Serious outcome risk
Outcome (studies)
Improvement
Relative risk · 95% CI
All studies (54)23%
Mortality (41)22%
Ventilation (10)29%
ICU admission (9)34%
Hospitalization (20)17%
Progression (6)21%
Recovery (16)21%
Cases (4)−9%
RCTs (30)18%
RCT mortality (22)5%
Prophylaxis (9)12%
Early (3)45%
Late (42)23%
Abstract
Significantly lower risk is seen for mortality, ICU admission, hospitalization, and recovery. 24 studies from 24 independent teams in 14 countries show significant
benefit.
Meta-analysis using the most serious outcome reported shows
23% [14‑31%] lower risk. Results are similar for higher quality and peer-reviewed studies and worse for Randomized Controlled Trials.
Clinical outcomes suggest benefit while viral and case outcomes do not, consistent with an intervention that aids the immune system or recovery but may have limited antiviral effects. Early treatment is more effective than late treatment.
Results are robust—in worst case exclusion sensitivity analysis 21 of 54
studies must be excluded before statistical significance is lost.
Emergent results for the efficacy gradient across outcomes (p = 0.045) that match the biological mechanisms confirm efficacy.
Colchicine for COVID-19
Serious outcome risk
Outcome (studies)
Improvement
Relative risk · 95% CI
All studies (54)23%
Mortality (41)22%
Ventilation (10)29%
ICU admission (9)34%
Hospitalization (20)17%
Progression (6)21%
Recovery (16)21%
Cases (4)−9%
RCTs (30)18%
RCT mortality (22)5%
Prophylaxis (9)12%
Early (3)45%
Late (42)23%
RCT results are less favorable, however they are dominated by the very late stage RECOVERY RCT which
is not generalizable to earlier usage.
No treatment is 100%
effective. Protocols combine safe and effective options with individual
risk/benefit analysis and monitoring.
Other treatments are more effective.
All data and sources to reproduce this analysis are in the appendix.
Colchicine for COVID-19
Highlights- Colchicine reduces risk with very high confidence for mortality, hospitalization, recovery, and in pooled analysis, high confidence for ICU admission, and very low confidence for ventilation.
- Emergent results for the efficacy gradient across outcomes (p = 0.045) that match the biological mechanisms confirm efficacy.
- Early treatment is more effective than late treatment.
- 5th treatment shown effective in September 2020, now with p = 0.0000049 from 54 studies.
- Real-time updates and corrections with a consistent protocol for 227 treatments. Outcome specific analysis and combined evidence from all studies including treatment delay, a primary confounding factor.
A
Colchicine COVID-19 studies
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Hunt68%0.32 · 0.15–0.67death
Hassan (RCT)−40%1.40 · 0.48–4.12hosp.7/505/50
Inokuchi (RCT)67%0.33 · 0.03–3.29hosp.1/232/15OT1 CT2
Early treatment45%0.55 · 0.18–1.678/737/6545% lower risk
Tau² = 0.57, I² = 62.8%, p = 0.3
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Brunetti (PSM)73%0.27 · 0.08–0.89death3/3311/33
Scarsi85%0.15 · 0.06–0.37death122 (n)140 (n)
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Pinzón35%0.65 · 0.34–1.21death14/14523/156
Sandhu42%0.58 · 0.40–0.85death16/3463/78
Rodriguez-Nava6%0.94 · 0.61–1.47death16/5285/261
Mahale−7%1.07 · 0.59–1.96death11/3925/95
Valerio Pas.. (ICU)23%0.77 · 0.31–1.94death5/3512/30ICU patients CT2
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Mareev80%0.20 · 0.01–4.01death0/212/22
Manenti (PSW)76%0.24 · 0.09–0.67death71 (n)70 (n)
Horby (RCT)−1%1.01 · 0.94–1.08death1,394/5,6101,408/5,730RECOVERY
Hueda-Zavaleta54%0.46 · 0.23–0.91death10/50109/301
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Diaz (RCT)12%0.88 · 0.70–1.12death131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Karakaş13%0.87 · 0.46–1.64death16/16519/171
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29death264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Hueda-Zavaleta−33%1.33 · 0.75–2.36death18/5233/148Ventilated patients
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Shah (RCT)−75%1.75 · 0.53–5.83death7/1254/125COLSTATCT2
Villamañán42%0.58 · 0.33–0.96death19/11132/111
Mehrizi−13%1.13 · 1.08–1.19deathpopulation-based cohort
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Vaziri (RCT)81%0.19 · 0.04–0.88death2/1087/71CT2
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment23%0.77 · 0.68–0.872,010/14,3252,360/15,08023% lower risk
Tau² = 0.04, I² = 68.9%, p < 0.0001
Madrid-García−37%1.37 · 0.48–3.90deathn/an/a
Ozcifci4%0.96 · 0.75–1.22cases130/61685/421
Monserrat .. (PSM)80%0.20 · 0.02–0.93deathn/an/a
Topless23%0.77 · 0.56–1.07deathpopulation-based cohort
Oztas−406%5.06 · 0.59–43.22hosp.5/6351/643
Avanoglu Guler79%0.21 · 0.04–0.83oxygen6/663/7
Correa-Rodríguez−150%2.50 · 0.10–60.63oxygen1/1630/81
Sáenz-Aldea−8%1.08 · 0.76–1.53hosp.case-control study
Chevalier−28%1.28 · 0.51–2.35death5/21111/569
Prophylaxis12%0.88 · 0.64–1.21147/1,501200/1,72112% lower risk
Tau² = 0.09, I² = 53.4%, p = 0.43
All studies23%0.77 · 0.69–0.862,165/15,8992,567/16,86623% lower risk
Tau² = 0.05, I² = 67.7%, p < 0.000100.511.52+
B
Loading..
Fig. 1. A. Random-effects meta-analysis. This plot shows pooled effects,
see the specific outcome analyses for individual outcomes.
Analysis validating pooled outcomes for
COVID-19 can be found below.
Effect extraction is pre-specified, using the most serious outcome reported.
For details see the appendix.
B. Timeline of results in colchicine studies. The marked dates indicate the time when efficacy was known with a statistically significant improvement of ≥10% from ≥3 studies for pooled outcomes, one or more specific outcome, pooled outcomes in RCTs, and one or more specific outcome in RCTs. Efficacy based on RCTs only was delayed by 4.4 months, compared to using all studies.
SARS-CoV-2 infection primarily begins in the upper respiratory
tract and may progress to the lower respiratory tract, other tissues, and the
nervous and cardiovascular systems, which may lead to cytokine storm,
pneumonia, ARDS, neurological injury12-28 and
cognitive deficits15,20, cardiovascular
complications29-35, DNA
damage36-39, organ failure, and death.
Even mild untreated infections may result in persistent cognitive
deficits40—the spike protein binds to fibrin leading to
fibrinolysis-resistant blood clots, thromboinflammation, and
neuropathology.
Minimizing replication as early as possible is recommended.
SARS-CoV-2 infection and replication involves the complex interplay of 500+
host and viral proteins and other factorsA,41-48 , providing many
therapeutic targets for which many existing compounds have known activity.
Scientists have predicted that over 12,000 compounds may
reduce COVID-19 risk49, either by
directly minimizing infection or replication, by supporting immune system
function, or by minimizing secondary complications.
We analyze all significant
controlled studies of
colchicine
for COVID-19.
Search methods, inclusion criteria, effect extraction criteria (more serious
outcomes have priority), all individual study data, PRISMA answers, and
statistical methods are detailed in Appendix 1. We present random-effects
meta-analysis results for all studies, studies within each treatment stage, individual outcomes, peer-reviewed studies, Randomized Controlled Trials (RCTs), and higher quality studies.
Fig. 3 shows stages of possible treatment for
COVID-19. Prophylaxis refers to regularly taking medication before
becoming sick, in order to prevent or minimize infection. Early
treatment refers to treatment immediately or soon after symptoms appear,
while late treatment refers to more delayed treatment.
Fig. 3. Treatment stages.
Table 1 shows potential mechanisms of action for
the treatment of COVID-19 using colchicine.
Colchicine: potential mechanisms of action for COVID-19
Antiviral effects
Direct antiviral activity via inhibiting microtubule polymerization and viral entry.
Immunomodulatory effects
Potential prevention of an overactive immune response via modulation of immune cell functions, such as neutrophil chemotaxis, adhesion, and activation.
Anti-inflammatory effects
Reduction in inflammation and severity of cytokine storm via inibition of inflammasome activation and the release of pro-inflammatory cytokines, including IL-1β, IL-6, and TNF-α.
Prevention of microvascular thrombosis
Reduction in the risk of clot formation via antithrombotic properties, such as inhibiting platelet aggregation.
Cardioprotective effects
Mitigation of myocardial injury via reduced myocardial inflammation and oxidative stress, and inhibition of NLRP3 inflammasomes.
Table 1. Colchicine mechanisms of action.
An in silico study supports the efficacy of colchicine57.
An in vitro study supports the efficacy of colchicine30.
Preclinical research is an important part of the development of
treatments, however results may be very different in clinical trials.
Preclinical results are not used in this paper.
Table 2 summarizes the results for all studies, for Randomized Controlled Trials, for peer-reviewed studies, with different exclusions, for specific outcomes, and by treatment stage.
Fig. 4 plots individual results by treatment stage.
Fig. 5, 6, 7, 8, 9, 10, 11, 12, 13, and 14
show forest plots for random-effects meta-analysis of
all studies with pooled effects, mortality results, ventilation, ICU admission, hospitalization, progression, recovery, cases, viral clearance, and peer reviewed studies.
Colchicine for COVID-19: meta-analysis results
November 2026
All stages
Prophylaxis
Early treatment
Late treatment
All studies54 studies · 33K patients
All stages0.77*** 0.69–0.8623% lower risk
Prophylaxis0.88 0.64–1.2112% lower risk
Early treatment0.55 0.18–1.6745% lower risk
Late treatment0.77*** 0.68–0.8723% lower risk
After exclusions43 studies · 15K patients
All stages0.69*** 0.59–0.8131% lower risk
Prophylaxis0.86 0.63–1.1614% lower risk
Early treatment0.55 0.18–1.6745% lower risk
Late treatment0.66*** 0.54–0.8034% lower risk
Peer-reviewed52 studies · 32K patients
All stages0.77*** 0.69–0.8623% lower risk
Prophylaxis0.88 0.64–1.2112% lower risk
Early treatment0.32*** 0.17–0.6068% lower risk
Late treatment0.77*** 0.68–0.8723% lower risk
RCTs30 studies · 27K patients
All stages0.82** 0.72–0.9318% lower risk
Prophylaxis—
Early treatment0.98 0.29–3.352% lower risk
Late treatment0.82** 0.72–0.9318% lower risk
RCTs after exclusions24 studies · 11K patients
All stages0.74*** 0.65–0.8426% lower risk
Prophylaxis—
Early treatment0.98 0.29–3.352% lower risk
Late treatment0.73*** 0.64–0.8327% lower risk
Mortality41 studies · 29K patients
All stages0.78*** 0.69–0.8822% lower risk
Prophylaxis0.82 0.46–1.4618% lower risk
Early treatment0.32** 0.15–0.6768% lower risk
Late treatment0.81*** 0.71–0.9119% lower risk
Ventilation10 studies · 14K patients
All stages0.71 0.44–1.1529% lower risk
Prophylaxis—
Early treatment—
Late treatment0.71 0.44–1.1529% lower risk
ICU admission9 studies · 1,389 patients
All stages0.66* 0.48–0.9234% lower risk
Prophylaxis—
Early treatment—
Late treatment0.66* 0.48–0.9234% lower risk
Hospitalization20 studies · 13K patients
All stages0.83*** 0.75–0.9117% lower risk
Prophylaxis1.10 0.84–1.4510% higher risk
Early treatment0.98 0.29–3.352% lower risk
Late treatment0.80*** 0.72–0.8820% lower risk
Recovery16 studies · 13K patients
All stages0.79** 0.68–0.9121% lower risk
Prophylaxis0.93 0.51–1.707% lower risk
Early treatment0.93 0.67–1.287% lower risk
Late treatment0.76** 0.65–0.9024% lower risk
Cases4 studies · 2,559 patients
All stages1.09 0.92–1.299% higher risk
Prophylaxis1.09 0.92–1.299% higher risk
Early treatment—
Late treatment—
RCT mortality22 studies · 26K patients
All stages0.95 0.85–1.055% lower risk
Prophylaxis—
Early treatment—
Late treatment0.95 0.85–1.055% lower risk
RCT hospitalization13 studies · 9,591 patients
All stages0.81*** 0.72–0.9219% lower risk
Prophylaxis—
Early treatment0.98 0.29–3.352% lower risk
Late treatment0.81*** 0.72–0.9119% lower risk
Random-effects meta-analysis. Relative risk with 95% CI. * p < 0.05, ** p < 0.01, *** p < 0.001.
Table 2. Random-effects meta-analysis results for colchicine. Results show the relative risk and 95% confidence interval.
Fig. 4. Scatter plot showing the most serious outcome in all studies, and for studies within each stage. Diamonds shows the results of random-effects meta-analysis.
Colchicine COVID-19 studies
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Hunt68%0.32 · 0.15–0.67death
Hassan (RCT)−40%1.40 · 0.48–4.12hosp.7/505/50
Inokuchi (RCT)67%0.33 · 0.03–3.29hosp.1/232/15OT1 CT2
Early treatment45%0.55 · 0.18–1.678/737/6545% lower risk
Tau² = 0.57, I² = 62.8%, p = 0.3
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Brunetti (PSM)73%0.27 · 0.08–0.89death3/3311/33
Scarsi85%0.15 · 0.06–0.37death122 (n)140 (n)
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Pinzón35%0.65 · 0.34–1.21death14/14523/156
Sandhu42%0.58 · 0.40–0.85death16/3463/78
Rodriguez-Nava6%0.94 · 0.61–1.47death16/5285/261
Mahale−7%1.07 · 0.59–1.96death11/3925/95
Valerio Pas.. (ICU)23%0.77 · 0.31–1.94death5/3512/30ICU patients CT2
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Mareev80%0.20 · 0.01–4.01death0/212/22
Manenti (PSW)76%0.24 · 0.09–0.67death71 (n)70 (n)
Horby (RCT)−1%1.01 · 0.94–1.08death1,394/5,6101,408/5,730RECOVERY
Hueda-Zavaleta54%0.46 · 0.23–0.91death10/50109/301
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Diaz (RCT)12%0.88 · 0.70–1.12death131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Karakaş13%0.87 · 0.46–1.64death16/16519/171
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29death264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Hueda-Zavaleta−33%1.33 · 0.75–2.36death18/5233/148Ventilated patients
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Shah (RCT)−75%1.75 · 0.53–5.83death7/1254/125COLSTATCT2
Villamañán42%0.58 · 0.33–0.96death19/11132/111
Mehrizi−13%1.13 · 1.08–1.19deathpopulation-based cohort
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Vaziri (RCT)81%0.19 · 0.04–0.88death2/1087/71CT2
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment23%0.77 · 0.68–0.872,010/14,3252,360/15,08023% lower risk
Tau² = 0.04, I² = 68.9%, p < 0.0001
Madrid-García−37%1.37 · 0.48–3.90deathn/an/a
Ozcifci4%0.96 · 0.75–1.22cases130/61685/421
Monserrat .. (PSM)80%0.20 · 0.02–0.93deathn/an/a
Topless23%0.77 · 0.56–1.07deathpopulation-based cohort
Oztas−406%5.06 · 0.59–43.22hosp.5/6351/643
Avanoglu Guler79%0.21 · 0.04–0.83oxygen6/663/7
Correa-Rodríguez−150%2.50 · 0.10–60.63oxygen1/1630/81
Sáenz-Aldea−8%1.08 · 0.76–1.53hosp.case-control study
Chevalier−28%1.28 · 0.51–2.35death5/21111/569
Prophylaxis12%0.88 · 0.64–1.21147/1,501200/1,72112% lower risk
Tau² = 0.09, I² = 53.4%, p = 0.43
All studies23%0.77 · 0.69–0.862,165/15,8992,567/16,86623% lower risk
Tau² = 0.05, I² = 67.7%, p < 0.000100.511.52+
Fig. 5. Random-effects meta-analysis for all studies.
This plot shows pooled effects,
see the specific outcome analyses for individual outcomes.
Analysis validating pooled outcomes for
COVID-19 can be found below.
Effect extraction is pre-specified, using the most serious outcome reported.
For details see the appendix.
Colchicine COVID-19 mortality results
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Early treatment68%0.32 · 0.17–0.6168% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.0006
Deftereos (RCT)77%0.23 · 0.03–1.971/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.030/362/36
Brunetti (PSM)73%0.27 · 0.08–0.893/3311/33
Scarsi85%0.15 · 0.06–0.37122 (n)140 (n)
Pinzón35%0.65 · 0.34–1.2114/14523/156
Sandhu42%0.58 · 0.40–0.8516/3463/78
Rodriguez-Nava6%0.94 · 0.61–1.4716/5285/261
Mahale−7%1.07 · 0.59–1.9611/3925/95
Valerio Pas.. (ICU)23%0.77 · 0.31–1.945/3512/30ICU patients CT1
Tardif (DB RCT)44%0.56 · 0.19–1.675/2,2359/2,253COLCORONA
Mareev80%0.20 · 0.01–4.010/212/22
Manenti (PSW)76%0.24 · 0.09–0.6771 (n)70 (n)
Horby (RCT)−1%1.01 · 0.94–1.081,394/5,6101,408/5,730RECOVERY
Hueda-Zavaleta54%0.46 · 0.23–0.9110/50109/301
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.3622/15328/161CT1
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.030/522/51
Dorward (RCT)70%0.30 · 0.01–7.370/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.404/566/60
Diaz (RCT)12%0.88 · 0.70–1.12131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.073/147/21
Karakaş13%0.87 · 0.46–1.6416/16519/171
Gorial (RCT)67%0.33 · 0.04–3.141/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.050/142/16STRUCK
Cecconi (DB RCT)29%0.71 · 0.28–1.797/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.4712/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.117/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.924/14613/146
Hueda-Zavaleta−33%1.33 · 0.75–2.3618/5233/148Ventilated patients
Kasiri (DB RCT)7%0.93 · 0.32–2.696/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.601/620/43
Shah (RCT)−75%1.75 · 0.53–5.837/1254/125COLSTATCT1
Villamañán42%0.58 · 0.33–0.9619/11132/111
Mehrizi−13%1.13 · 1.08–1.19population-based cohort
Yadollahza.. (RCT)33%0.67 · 0.28–1.606/269/26
Vaziri (RCT)81%0.19 · 0.04–0.882/1087/71CT1
Late treatment19%0.81 · 0.71–0.912,005/13,9922,342/14,73919% lower risk
Tau² = 0.03, I² = 63.7%, p = 0.00081
Madrid-García−37%1.37 · 0.48–3.90n/an/a
Monserrat .. (PSM)80%0.20 · 0.02–0.93n/an/a
Topless23%0.77 · 0.56–1.07population-based cohort
Chevalier−28%1.28 · 0.51–2.355/21111/569
Prophylaxis18%0.82 · 0.46–1.465/21111/56918% lower risk
Tau² = 0.17, I² = 52.6%, p = 0.51
All studies22%0.78 · 0.69–0.882,010/14,0132,453/15,30822% lower risk
Tau² = 0.04, I² = 66.3%, p < 0.000100.511.52+
Fig. 6. Random-effects meta-analysis for mortality results.
Colchicine COVID-19 mechanical ventilation results
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Deftereos (RCT)82%0.18 · 0.02–1.501/555/50GRECCO-19
Sandhu53%0.47 · 0.33–0.6716/3468/68
Tardif (DB RCT)47%0.53 · 0.25–1.0911/2,23521/2,253COLCORONA
Horby (RCT)−18%1.18 · 0.99–1.40259/3,815228/3,962RECOVERY
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.030/522/51
Cecconi (DB RCT)50%0.50 · 0.18–1.435/11910/120
Perricone (RCT)−30%1.30 · 0.30–5.614/773/75COLVID-19
Rahman (DB RCT)51%0.49 · 0.09–2.682/1464/146
Kasiri (DB RCT)7%0.93 · 0.32–2.696/556/51
Shah (RCT)−200%3.00 · 0.62–14.586/1252/125COLSTATCT1
Late treatment29%0.71 · 0.44–1.15310/6,713349/6,90129% lower risk
Tau² = 0.27, I² = 71.4%, p = 0.16
All studies29%0.71 · 0.44–1.15310/6,713349/6,90129% lower risk
Tau² = 0.27, I² = 71.4%, p = 0.1600.511.52+
Fig. 7. Random-effects meta-analysis for ventilation.
Colchicine COVID-19 ICU results
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Lopes (DB RCT)50%0.50 · 0.10–2.562/364/36
Valerio Pas.. (ICU)40%0.60 · 0.38–0.9535 (n)30 (n)ICU patients CT1
Pascual-Fi.. (RCT)51%0.49 · 0.09–2.562/524/51
Karakaş16%0.84 · 0.55–1.2930/16537/171
Cecconi (DB RCT)21%0.79 · 0.38–1.6711/11914/120
Perricone (RCT)76%0.24 · 0.03–2.131/774/75COLVID-19
Kasiri (DB RCT)−24%1.24 · 0.57–2.6912/559/51
Vaziri (RCT)87%0.13 · 0.03–0.582/10810/71CT1
Gertner (RCT)65%0.35 · 0.10–1.2767 (n)70 (n)COLTREXONE
Late treatment34%0.66 · 0.48–0.9260/71482/67534% lower risk
Tau² = 0.05, I² = 23.7%, p = 0.013
All studies34%0.66 · 0.48–0.9260/71482/67534% lower risk
Tau² = 0.05, I² = 23.7%, p = 0.01300.511.52+
Fig. 8. Random-effects meta-analysis for ICU admission.
Colchicine COVID-19 hospitalization results
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment2%0.98 · 0.29–3.358/737/652% lower risk
Tau² = 0.22, I² = 20.3%, p = 0.98
Lopes (DB RCT)22%0.78 · 0.64–0.94hosp. time36 (n)36 (n)
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Tardif (DB RCT)20%0.80 · 0.61–1.03hosp.101/2,235128/2,253COLCORONA
Mareev26%0.74 · 0.53–1.04hosp. time21 (n)22 (n)
Pascual-Fi.. (RCT)−15%1.15 · 0.87–1.51hosp. time52 (n)51 (n)
Karakaş25%0.75 · 0.65–0.87hosp. time165 (n)171 (n)
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Eikelboom (RCT)−2%1.02 · 0.71–1.45hosp.62/1,93961/1,942ACT outpatient
Perricone (RCT)4%0.96 · 0.79–1.17hosp. time77 (n)75 (n)COLVID-19
Vaziri (RCT)35%0.65 · 0.58–0.73hosp. time108 (n)71 (n)CT2
Gertner (RCT)20%0.80 · 0.59–1.07hosp. time67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment20%0.80 · 0.72–0.88168/4,918207/4,91420% lower risk
Tau² = 0.02, I² = 57.0%, p < 0.0001
Madrid-García−137%2.37 · 0.64–8.73hosp.n/an/a
Oztas−406%5.06 · 0.59–43.22hosp.5/6351/643
Correa-Rodríguez−150%2.50 · 0.10–60.63hosp.1/1630/81
Sáenz-Aldea−8%1.08 · 0.76–1.53hosp.case-control study
Chevalier8%0.92 · 0.36–1.78hosp.15/116180/1,097
Prophylaxis−10%1.10 · 0.84–1.4521/914181/1,82110% higher risk
Tau² = 0.00, I² = 0.9%, p = 0.51
All studies17%0.83 · 0.75–0.91197/5,905395/6,80017% lower risk
Tau² = 0.02, I² = 52.5%, p = 0.0002100.511.52+
Fig. 9. Random-effects meta-analysis for hospitalization.
Colchicine COVID-19 progression results
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Deftereos (RCT)87%0.13 · 0.01–0.971/557/50GRECCO-19
Absalón-.. (DB RCT)17%0.83 · 0.35–1.9356 (n)60 (n)
Eikelboom (RCT)−4%1.04 · 0.90–1.21368/1,304356/1,307ACT inpatient
Perricone (RCT)−7%1.07 · 0.48–2.3711/7710/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.924/14613/146
Sunil Naik (RCT)−108%2.08 · 0.22–19.343/621/43
Late treatment21%0.79 · 0.49–1.28387/1,700387/1,68121% lower risk
Tau² = 0.15, I² = 48.7%, p = 0.34
All studies21%0.79 · 0.49–1.28387/1,700387/1,68121% lower risk
Tau² = 0.15, I² = 48.7%, p = 0.3400.511.52+
Fig. 10. Random-effects meta-analysis for progression.
Colchicine COVID-19 recovery results
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Hassan (RCT)4%0.96 · 0.68–1.37no recov.27/5028/50
Inokuchi (RCT)24%0.76 · 0.35–1.67no recov.8/216/12OT1 CT2
Early treatment7%0.93 · 0.67–1.2835/7134/627% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.66
Brunetti (PSM)73%0.27 · 0.08–0.89no disch.3/3311/33
Sandhu42%0.58 · 0.40–0.85no disch.16/3463/78
Mareev50%0.50 · 0.24–1.04no recov.21 (n)22 (n)
Manenti (PSW)44%0.56 · 0.31–1.00no recov.71 (n)70 (n)
Horby (RCT)−2%1.02 · 0.97–1.06no disch.1,709/5,6101,698/5,730RECOVERY
Dorward (RCT)−6%1.06 · 0.81–1.39no recov.156 (n)133 (n)PRINCIPLE
Absalón-.. (DB RCT)−13%1.13 · 0.76–1.66no recov.56 (n)60 (n)
Pourdowlat (RCT)38%0.62 · 0.41–0.94no recov.89 (n)63 (n)
Gorial (RCT)63%0.37 · 0.21–0.67no recov.80 (n)80 (n)
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)28%0.72 · 0.29–1.79no recov.7/559/51
Sunil Naik (RCT)7%0.93 · 0.82–1.04no recov.62 (n)43 (n)
Gertner (RCT)43%0.57 · 0.27–1.20no recov.67 (n)70 (n)COLTREXONE
Late treatment24%0.76 · 0.65–0.901,735/6,3821,781/6,48124% lower risk
Tau² = 0.04, I² = 71.5%, p = 0.0012
Prophylaxis7%0.93 · 0.51–1.7013/247/127% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.82
All studies21%0.79 · 0.68–0.911,783/6,4771,822/6,55521% lower risk
Tau² = 0.03, I² = 64.6%, p = 0.001400.511.52+
Fig. 11. Random-effects meta-analysis for recovery.
Colchicine COVID-19 case results
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Ozcifci4%0.96 · 0.75–1.22cases130/61685/421
Oztas−73%1.73 · 0.96–3.11symp. case29/63517/643
Correa-Rodríguez1%0.99 · 0.52–1.88cases24/16312/81
Sáenz-Aldea−12%1.12 · 0.91–1.37casescase-control study
Prophylaxis−9%1.09 · 0.92–1.29183/1,414114/1,1459% higher risk
Tau² = 0.01, I² = 15.5%, p = 0.33
All studies−9%1.09 · 0.92–1.29183/1,414114/1,1459% higher risk
Tau² = 0.01, I² = 15.5%, p = 0.3300.511.52+
Fig. 12. Random-effects meta-analysis for cases.
Colchicine COVID-19 viral clearance results
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Late treatment11%0.89 · 0.42–1.8730 (n)29 (n)11% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.77
All studies11%0.89 · 0.42–1.8730 (n)29 (n)11% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.7700.511.52+
Fig. 13. Random-effects meta-analysis for viral clearance.
Colchicine COVID-19 peer reviewed studies
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment68%0.32 · 0.17–0.601/232/1568% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.00038
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Brunetti (PSM)73%0.27 · 0.08–0.89death3/3311/33
Scarsi85%0.15 · 0.06–0.37death122 (n)140 (n)
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Sandhu42%0.58 · 0.40–0.85death16/3463/78
Rodriguez-Nava6%0.94 · 0.61–1.47death16/5285/261
Mahale−7%1.07 · 0.59–1.96death11/3925/95
Valerio Pas.. (ICU)23%0.77 · 0.31–1.94death5/3512/30ICU patients CT2
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Mareev80%0.20 · 0.01–4.01death0/212/22
Manenti (PSW)76%0.24 · 0.09–0.67death71 (n)70 (n)
Horby (RCT)−1%1.01 · 0.94–1.08death1,394/5,6101,408/5,730RECOVERY
Hueda-Zavaleta54%0.46 · 0.23–0.91death10/50109/301
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Diaz (RCT)12%0.88 · 0.70–1.12death131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Karakaş13%0.87 · 0.46–1.64death16/16519/171
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29death264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Hueda-Zavaleta−33%1.33 · 0.75–2.36death18/5233/148Ventilated patients
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Shah (RCT)−75%1.75 · 0.53–5.83death7/1254/125COLSTATCT2
Villamañán42%0.58 · 0.33–0.96death19/11132/111
Mehrizi−13%1.13 · 1.08–1.19deathpopulation-based cohort
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Vaziri (RCT)81%0.19 · 0.04–0.88death2/1087/71CT2
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment23%0.77 · 0.68–0.871,996/14,1802,337/14,92423% lower risk
Tau² = 0.04, I² = 69.2%, p < 0.0001
Madrid-García−37%1.37 · 0.48–3.90deathn/an/a
Ozcifci4%0.96 · 0.75–1.22cases130/61685/421
Monserrat .. (PSM)80%0.20 · 0.02–0.93deathn/an/a
Topless23%0.77 · 0.56–1.07deathpopulation-based cohort
Oztas−406%5.06 · 0.59–43.22hosp.5/6351/643
Avanoglu Guler79%0.21 · 0.04–0.83oxygen6/663/7
Correa-Rodríguez−150%2.50 · 0.10–60.63oxygen1/1630/81
Sáenz-Aldea−8%1.08 · 0.76–1.53hosp.case-control study
Chevalier−28%1.28 · 0.51–2.35death5/21111/569
Prophylaxis12%0.88 · 0.64–1.21147/1,501200/1,72112% lower risk
Tau² = 0.09, I² = 53.4%, p = 0.43
All studies23%0.77 · 0.69–0.862,144/15,7042,539/16,66023% lower risk
Tau² = 0.05, I² = 68.5%, p < 0.000100.511.52+
Fig. 14. Random-effects meta-analysis for peer reviewed studies.
Zeraatkar et al. analyze 356 COVID-19 trials, finding no significant
evidence that preprint results are inconsistent with peer-reviewed studies.
They also show extremely long peer-review delays, with a median of 6 months to
journal publication. A six month delay was equivalent to around 1.5 million
deaths during the first two years of the pandemic. Authors recommend using
preprint evidence, with appropriate checks for potential falsified data, which
provides higher certainty much earlier. Davidson et al. also showed no
important difference between meta-analysis results of preprints and
peer-reviewed publications for COVID-19, based on 37 meta-analyses including
114 trials.
Effect extraction is pre-specified, using the most serious outcome reported,
see the appendix for details.
Analysis validating pooled outcomes for
COVID-19 can be found below.
Fig. 15 shows a comparison of results for RCTs and observational studies.
Fig. 16, 17, 18, 19, and 20
show forest plots for random-effects meta-analysis of
all Randomized Controlled Trials, RCTs after exclusions, RCT mortality results, RCT mortality results after exclusions, and RCT hospitalization results.
RCT results are included in Table 2.
Fig. 15. Results for RCTs and observational studies.
RCTs help to make study groups more similar and can provide a higher level of
evidence, however they are subject to many biases60, and
analysis of double-blind RCTs has identified extreme levels of bias61.
For COVID-19, the overhead may delay treatment, dramatically compromising
efficacy; they may encourage monotherapy for simplicity at the cost of
efficacy which may rely on combined or synergistic effects; the participants
that sign up may not reflect real world usage or the population that benefits
most in terms of age, comorbidities, severity of illness, or other factors;
standard of care may be compromised and unable to evolve quickly based on
emerging research for new diseases; errors may be made in randomization and
medication delivery; and investigators may have hidden agendas or vested
interests influencing design, operation, analysis, reporting, and the
potential for fraud. All of these biases have been observed with COVID-19
RCTs. There is no guarantee that a specific RCT provides a higher level of
evidence.
RCTs are expensive and many RCTs are funded
by pharmaceutical companies or other organizations with conflicts of interest, for example
governments that previously denied treatment with the study drug.
For COVID-19, this creates an incentive to show efficacy for
patented commercial products, and an incentive to show a lack of efficacy for
inexpensive treatments. The bias is expected to be significant, for example
Als-Nielsen et al. analyzed 370 RCTs from Cochrane reviews, showing that
trials funded by for-profit organizations were 5 times more likely to
recommend the experimental drug compared with those funded by nonprofit
organizations. Bekelman et al. and Lundh et al. show that
industry-sponsored studies are more likely to be favorable.
For COVID-19, some major philanthropic organizations are
largely funded by investments with extreme conflicts of interest for and
against specific COVID-19 interventions.
High quality RCTs for novel acute diseases are more challenging, with
increased ethical issues due to the urgency of treatment, increased risk due
to enrollment delays, and more difficult design with a rapidly evolving
evidence base. For COVID-19, the most common site of initial infection is the
upper respiratory tract. Immediate treatment is likely to be most successful
and may prevent or slow progression to other parts of the body. For a
non-prophylaxis RCT, it makes sense to provide treatment in advance and
instruct patients to use it immediately on symptoms, just as some governments
have done by providing medication kits in advance. Unfortunately, no RCTs have
been done in this way. Every treatment RCT to date involves delayed treatment.
Among the 227 treatments we have analyzed,
67% of RCTs involve very late treatment 5+ days after
onset. No non-prophylaxis COVID-19 RCTs match the potential real-world use of
early treatments. They may more accurately represent results for treatments
that require visiting a medical facility, e.g., those requiring intravenous
administration.
RCTs have a bias against finding an effect for interventions
that are widely available—patients that believe they need the
intervention are more likely to decline participation and take the
intervention. RCTs for colchicine are more likely to enroll low-risk
participants that do not need treatment to recover, making the results less
applicable to clinical practice. This bias is likely to be greater for widely
known treatments, and may be greater when the risk of a serious outcome is
overstated. This bias does not apply to the typical pharmaceutical trial of a
new drug that is otherwise unavailable.
COVID-19 RCT vs. observational results from 6,000+ studies
November 2026
RR · CI
All treatments0.97 · 0.91–1.03
00.511.52
Evidence shows that observational studies
can also provide reliable results. Concato et al. found that well-designed
observational studies do not systematically overestimate the magnitude of the
effects of treatment compared to RCTs. Anglemyer et al. analyzed reviews
comparing RCTs to observational studies and found little evidence for
significant differences in effect estimates.
We performed a similar analysis across the 227 treatments
we cover, showing no significant difference in the results of RCTs compared to
observational studies, RR 0.97 [0.91‑1.03]54. Similar results are found for all low-cost treatments, RR
0.98 [0.90‑1.06]. High-cost treatments
show a non-significant trend towards RCTs showing greater efficacy,
RR 0.92 [0.84‑1.02].
Details can be found in the
supplementary data.
Lee et al. showed that only 14% of the guidelines of the Infectious
Diseases Society of America were based on RCTs. Evaluation of studies relies
on an understanding of the study and potential biases. Limitations in an RCT
can outweigh the benefits, for example excessive dosages, excessive treatment
delays, or remote survey bias may have a greater effect on results. Ethical
issues may also prevent running RCTs for known effective treatments. For more
on issues with RCTs see69,70.
Concato et al. report a paradoxical finding—RCT results had higher
variability, and only RCTs were found to sometimes report significant results the opposite
of the overall result. The same trend is seen for the most popular (most politicized)
COVID-19 treatments—considering all statistically significant results reported in
studies, RCTs are slightly more likely to report a result in the opposite direction. In
other words, for these COVID-19 treatments and for the topics covered by Concato et al., assuming causality from a single study is more likely to result in an incorrect conclusion for
RCTs.
Increased risk of inconsistent results for RCTs suggests higher prevalence of
bias, which may arise due to many issues including design bias, conflicts of interest,
treatment differences by physicians aware of allocation, attrition bias, ascertainment
bias, randomization failures, errors, or fraud.
Currently, 59 of the treatments we analyze show statistically significant efficacy or harm, defined as ≥10% decreased risk or >0% increased risk from ≥3 studies. Of these, 54% have been confirmed in RCTs, with a mean delay of 7.8 months (62% with 8.7 months delay for low-cost treatments). The remaining treatments either have no RCTs, or the point estimate is consistent.
Neither observational studies nor RCTs prove causation—any study can be
flawed or fraudulent. We need much more, for example a combination of results from many
independent teams, detailed understanding of each study, knowledge of conflicts/team
reliability, dose-response relationships, delay-response relationships, logical results across outcomes, or details consistent with preclinical expectations.
All studies must be evaluated individually. RCTs for a
given medication and disease may be more reliable, however they may also be
less reliable. For off-patent medications, very high conflict of interest
trials may be more likely to be RCTs, and more likely to be large trials that
dominate meta-analyses.
Colchicine COVID-19 Randomized Controlled Trials
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment2%0.98 · 0.29–3.358/737/652% lower risk
Tau² = 0.22, I² = 20.3%, p = 0.98
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Horby (RCT)−1%1.01 · 0.94–1.08death1,394/5,6101,408/5,730RECOVERY
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Diaz (RCT)12%0.88 · 0.70–1.12death131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29death264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Shah (RCT)−75%1.75 · 0.53–5.83death7/1254/125COLSTATCT2
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Vaziri (RCT)81%0.19 · 0.04–0.88death2/1087/71CT2
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment18%0.82 · 0.72–0.931,882/13,3951,946/13,46418% lower risk
Tau² = 0.02, I² = 44.7%, p = 0.0023
All studies18%0.82 · 0.72–0.931,890/13,4681,953/13,52918% lower risk
Tau² = 0.02, I² = 42.1%, p = 0.002500.511.52+
Fig. 16. Random-effects meta-analysis for all Randomized Controlled Trials.
This plot shows pooled effects,
see the specific outcome analyses for individual outcomes.
Analysis validating pooled outcomes for
COVID-19 can be found below.
Effect extraction is pre-specified, using the most serious outcome reported.
For details see the appendix.
Colchicine COVID-19 Randomized Controlled Trials after exclusions
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment2%0.98 · 0.29–3.358/737/652% lower risk
Tau² = 0.22, I² = 20.3%, p = 0.98
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment27%0.73 · 0.64–0.8384/5,572136/5,54827% lower risk
Tau² = 0.00, I² = 0.0%, p < 0.0001
All studies26%0.74 · 0.65–0.8492/5,645143/5,61326% lower risk
Tau² = 0.00, I² = 0.0%, p < 0.000100.511.52+
Colchicine COVID-19 RCT mortality results
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Deftereos (RCT)77%0.23 · 0.03–1.971/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.030/362/36
Tardif (DB RCT)44%0.56 · 0.19–1.675/2,2359/2,253COLCORONA
Horby (RCT)−1%1.01 · 0.94–1.081,394/5,6101,408/5,730RECOVERY
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.3622/15328/161CT1
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.030/522/51
Dorward (RCT)70%0.30 · 0.01–7.370/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.404/566/60
Diaz (RCT)12%0.88 · 0.70–1.12131/640142/639
Alsultan (RCT)36%0.64 · 0.20–2.073/147/21
Gorial (RCT)67%0.33 · 0.04–3.141/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.050/142/16STRUCK
Cecconi (DB RCT)29%0.71 · 0.28–1.797/11910/120
Eikelboom (RCT)−8%1.08 · 0.91–1.29264/1,304249/1,307ACT inpatient
Eikelboom (RCT)−9%1.09 · 0.48–2.4712/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.117/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.924/14613/146
Kasiri (DB RCT)7%0.93 · 0.32–2.696/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.601/620/43
Shah (RCT)−75%1.75 · 0.53–5.837/1254/125COLSTATCT1
Yadollahza.. (RCT)33%0.67 · 0.28–1.606/269/26
Vaziri (RCT)81%0.19 · 0.04–0.882/1087/71CT1
Late treatment5%0.95 · 0.85–1.051,877/13,0621,928/13,1235% lower risk
Tau² = 0.01, I² = 12.8%, p = 0.31
All studies5%0.95 · 0.85–1.051,877/13,0621,928/13,1235% lower risk
Tau² = 0.01, I² = 12.8%, p = 0.3100.511.52+
Fig. 18. Random-effects meta-analysis for RCT mortality results.
Colchicine COVID-19 RCT mortality results after exclusions
November 2026
StudyImprovementRR · 95% CITreatmentControlRelative Risk
Deftereos (RCT)77%0.23 · 0.03–1.971/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.030/362/36
Tardif (DB RCT)44%0.56 · 0.19–1.675/2,2359/2,253COLCORONA
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.3622/15328/161CT1
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.030/522/51
Dorward (RCT)70%0.30 · 0.01–7.370/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.404/566/60
Alsultan (RCT)36%0.64 · 0.20–2.073/147/21
Gorial (RCT)67%0.33 · 0.04–3.141/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.050/142/16STRUCK
Cecconi (DB RCT)29%0.71 · 0.28–1.797/11910/120
Eikelboom (RCT)−9%1.09 · 0.48–2.4712/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.117/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.924/14613/146
Kasiri (DB RCT)7%0.93 · 0.32–2.696/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.601/620/43
Yadollahza.. (RCT)33%0.67 · 0.28–1.606/269/26
Late treatment29%0.71 · 0.54–0.9379/5,275118/5,25129% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.012
All studies29%0.71 · 0.54–0.9379/5,275118/5,25129% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.01200.511.52+
Fig. 19. Random-effects meta-analysis for RCT mortality results after exclusions.
Colchicine COVID-19 RCT hospitalization results
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment2%0.98 · 0.29–3.358/737/652% lower risk
Tau² = 0.22, I² = 20.3%, p = 0.98
Lopes (DB RCT)22%0.78 · 0.64–0.94hosp. time36 (n)36 (n)
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Tardif (DB RCT)20%0.80 · 0.61–1.03hosp.101/2,235128/2,253COLCORONA
Pascual-Fi.. (RCT)−15%1.15 · 0.87–1.51hosp. time52 (n)51 (n)
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Jalal (RCT)24%0.76 · 0.62–0.93hosp. time36 (n)44 (n)
Eikelboom (RCT)−2%1.02 · 0.71–1.45hosp.62/1,93961/1,942ACT outpatient
Perricone (RCT)4%0.96 · 0.79–1.17hosp. time77 (n)75 (n)COLVID-19
Vaziri (RCT)35%0.65 · 0.58–0.73hosp. time108 (n)71 (n)CT2
Gertner (RCT)20%0.80 · 0.59–1.07hosp. time67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment19%0.81 · 0.72–0.91168/4,732207/4,72119% lower risk
Tau² = 0.02, I² = 64.0%, p = 0.00073
All studies19%0.81 · 0.72–0.92176/4,805214/4,78619% lower risk
Tau² = 0.02, I² = 59.2%, p = 0.0007600.511.52+
Fig. 20. Random-effects meta-analysis for RCT hospitalization results.
To avoid bias in the selection of studies, we analyze all
non-retracted studies. Here we show the results after excluding
studies with major issues likely to alter results, non-standard studies, and
studies where very minimal detail is currently available. Our bias evaluation
is based on analysis of each study and identifying when there is a significant
chance that limitations will substantially change the outcome of the study. We
believe this can be more valuable than checklist-based approaches such as
Cochrane GRADE, which can be easily influenced by potential bias, may ignore
or underemphasize serious issues not captured in the checklists, and may
overemphasize issues unlikely to alter outcomes in specific cases (for example
certain specifics of randomization with a very large effect size and
well-matched baseline characteristics).
The studies excluded are as below.
Fig. 22 shows a forest plot for random-effects
meta-analysis of all studies after exclusions.
Diaz, very late stage, oxygen saturation <90% at baseline; very late stage, >80% on oxygen/ventilation at baseline.
Eikelboom, very late stage, oxygen saturation <90% at baseline.
Horby, very late stage, 9 days since symptoms started, 32% baseline ventilation.
Jalal, minimal details provided.
Karakaş, excessive unadjusted differences between groups.
Mahale, unadjusted results with no group details.
Oztas, excessive unadjusted differences between groups.
Rodriguez-Nava, substantial unadjusted confounding by indication likely; excessive unadjusted differences between groups; unadjusted results with no group details.
Scarsi, significant confounding by time possible due to separation of groups in different time periods.
Shah, very late stage, >50% on oxygen/ventilation at baseline.
Vaziri, randomization resulted in significant baseline differences that were not adjusted for.
Colchicine COVID-19 studies after exclusions
November 2026
StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Hunt68%0.32 · 0.15–0.67death
Hassan (RCT)−40%1.40 · 0.48–4.12hosp.7/505/50
Inokuchi (RCT)67%0.33 · 0.03–3.29hosp.1/232/15OT1 CT2
Early treatment45%0.55 · 0.18–1.678/737/6545% lower risk
Tau² = 0.57, I² = 62.8%, p = 0.3
Deftereos (RCT)77%0.23 · 0.03–1.97death1/554/50GRECCO-19
Lopes (DB RCT)80%0.20 · 0.01–4.03death0/362/36
Brunetti (PSM)73%0.27 · 0.08–0.89death3/3311/33
Salehzadeh (RCT)23%0.77 · 0.66–0.90hosp. time50 (n)50 (n)
Pinzón35%0.65 · 0.34–1.21death14/14523/156
Sandhu42%0.58 · 0.40–0.85death16/3463/78
Valerio Pas.. (ICU)23%0.77 · 0.31–1.94death5/3512/30ICU patients CT2
Tardif (DB RCT)44%0.56 · 0.19–1.67death5/2,2359/2,253COLCORONA
Mareev80%0.20 · 0.01–4.01death0/212/22
Manenti (PSW)76%0.24 · 0.09–0.67death71 (n)70 (n)
Hueda-Zavaleta54%0.46 · 0.23–0.91death10/50109/301
Gaitán-Dua.. (RCT)22%0.78 · 0.44–1.36death22/15328/161CT2
Pascual-Fi.. (RCT)80%0.20 · 0.01–4.03death0/522/51
Dorward (RCT)70%0.30 · 0.01–7.37death0/1561/120PRINCIPLE
Absalón-.. (DB RCT)29%0.71 · 0.21–2.40death4/566/60
Alsultan (RCT)36%0.64 · 0.20–2.07death3/147/21
Pourdowlat (RCT)73%0.27 · 0.11–0.71hosp.5/10218/100
Gorial (RCT)67%0.33 · 0.04–3.14death1/803/80
Pimenta B.. (RCT)79%0.21 · 0.01–4.05death0/142/16STRUCK
Cecconi (DB RCT)29%0.71 · 0.28–1.79death7/11910/120
Eikelboom (RCT)−9%1.09 · 0.48–2.47death12/1,93911/1,942ACT outpatient
Perricone (RCT)−36%1.36 · 0.45–4.11death7/775/75COLVID-19
Rahman (DB RCT)71%0.29 · 0.10–0.92death4/14613/146
Hueda-Zavaleta−33%1.33 · 0.75–2.36death18/5233/148Ventilated patients
Haroon (RCT)34%0.66 · 0.40–1.10no recov.48 (n)48 (n)
Kasiri (DB RCT)7%0.93 · 0.32–2.69death6/556/51
Sunil Naik (RCT)−169%2.69 · 0.11–64.60death1/620/43
Villamañán42%0.58 · 0.33–0.96death19/11132/111
Mehrizi−13%1.13 · 1.08–1.19deathpopulation-based cohort
Yadollahza.. (RCT)33%0.67 · 0.28–1.60death6/269/26
Gertner (RCT)65%0.35 · 0.10–1.27ICU67 (n)70 (n)COLTREXONE
Landi (RCT)−4%1.04 · 0.06–16.56hosp.30 (n)29 (n)CONVINCE
Late treatment34%0.66 · 0.54–0.80169/6,124421/6,49734% lower risk
Tau² = 0.11, I² = 68.0%, p < 0.0001
Madrid-García−37%1.37 · 0.48–3.90deathn/an/a
Ozcifci4%0.96 · 0.75–1.22cases130/61685/421
Monserrat .. (PSM)80%0.20 · 0.02–0.93deathn/an/a
Topless23%0.77 · 0.56–1.07deathpopulation-based cohort
Avanoglu Guler79%0.21 · 0.04–0.83oxygen6/663/7
Correa-Rodríguez−150%2.50 · 0.10–60.63oxygen1/1630/81
Sáenz-Aldea−8%1.08 · 0.76–1.53hosp.case-control study
Chevalier−28%1.28 · 0.51–2.35death5/21111/569
Prophylaxis14%0.86 · 0.63–1.16142/866199/1,07814% lower risk
Tau² = 0.07, I² = 52.4%, p = 0.31
All studies31%0.69 · 0.59–0.81319/7,063627/7,64031% lower risk
Tau² = 0.10, I² = 67.2%, p < 0.000100.511.52+
Fig. 22. Random-effects meta-analysis for all studies after exclusions.
This plot shows pooled effects,
see the specific outcome analyses for individual outcomes.
Analysis validating pooled outcomes for
COVID-19 can be found below.
Effect extraction is pre-specified, using the most serious outcome reported.
For details see the appendix.
Preclinical research suggests that colchicine is more likely to be beneficial later
in infection rather than via a direct antiviral effect (host-directed efficacy).
For this kind of treatment, we may expect a gradient of efficacy across outcomes, with minimal impact on preventing
initial infection (PCR+ cases), but increasing efficacy as the disease progresses to more
severe stages.
For colchicine, random-effects meta-regression shows a significant association with
increasing efficacy for more severe outcomes. For every one-step increase in severity
(cases → hospitalization → critical outcomes: ICU, ventilation, and mortality),
meta-regression shows that the Risk Ratio decreases by a factor of
1.13 (slope β = -0.12
[-0.24 to -0.00]; p = 0.045). In other words, the protective effect becomes stronger as
the outcome becomes more critical.
The trend across outcomes is consistent with a beneficial effect due to
minimizing secondary complications rather than a direct antiviral effect.
This reinforces the reliability of the overall finding that colchicine
reduces risk for COVID-19.
If the observed efficacy was due to a systematic bias increasing the efficacy of outcomes,
it would not be expected to create a trend across outcomes that matches the biological
mechanism.
With 54 studies for colchicine, we can analyze trends across studies. A significant
interaction that matches the biological mechanisms provides further confirmation of
efficacy.
Analysis of the efficacy gradient across outcomes shows a significant interaction, with p = 0.045.
This reinforces the reliability of the overall finding that colchicine
reduces risk for COVID-19.
If the observed efficacy was due to a systematic bias increasing efficacy in results, we
would not expect analysis across studies to find this significant interaction
that matches the biological mechanisms.
Low-cost treatments were subject to bias and censorship during the pandemic.
Scientific bias is seen in the design, analysis, presentation, and selective
reporting of studies, which often favored negative results. A similar bias is seen in the media
coverage for low-cost treatments.
While broadly seen, bias was particularly notable for ivermectin and hydroxychloroquine, e.g., Scott Alexander noted that "if you say anything in favor of ivermectin you will be cast out of civilization and thrown into the circle of social hell reserved for Klan members and 1/6 insurrectionists. All the health officials in the world will shout 'horse dewormer!' at you and compare you to Josef Mengele."50.
We analyze media coverage for the 227 treatments we
cover using Altmetric82 and PlumX
Metrics83. Altmetric covers ~14,000
news outlets84 and PlumX covers
~55,000 news sources85.
The two services are complementary with coverage of different news sources and different
methods for identifying articles not containing a DOI. We consider studies to have
received significant media coverage if they were covered by at least 100 articles in
either Altmetric of PlumX85,86. The most widespread study was covered
by 1,047 outlets. Studies covered by major
syndicated sources shows hundreds of news articles, while studies covered by few outlets
typically appear in niche medical news sources or press releases.
Fig. 23 and 24 analyze coverage for all low-cost treatments and all high-profit treatments, showing significant bias.
For low-cost treatments media coverage favored negative results 5.4× more than positive results, whereas for high-profit treatments coverage favored positive results 3.8× more than negative results.
The media bias may result in widespread incorrect perceptions on the relative efficacy of high-profit and low-cost treatments. The impact is significant—increased cost limits the use of high-profit
treatments and treatment equity. High-profit treatments were also more difficult to access, especially for earlier treatment which improves efficacy and minimizes community transmission.
Media bias for low-cost COVID‑19 treatments
November 2026
Media covered only 0.8% of studies showing significantly lower COVID-19 risk
Only 5 positive studies were covered
2020
2021
2022
2023
2020
2021
2022
2023
0.8%
one each: budesonide, cannabidiol, fluvoxamine, HCQ, vitamin D
34 negative studies were covered
2020
2021
2022
2023
2020
2021
2022
2023
4%
HCQ 12, ivermectin 6, lopinavir/ritonavir 4, azithromycin 3, vitamin D 3, fluvoxamine 2, one each: ibuprofen, metformin, vitamin C, zinc
5.4×
Negative bias for low-cost treatments
negative studies were 5.4 times more likely to be coveredFig. 23. Mainstream media coverage was biased against positive results for low-cost treatments. When restricting to RCTs, the bias was even larger, with negative RCTs 6.9× more likely to be covered.
Media was 3.8× more likely to cover positive studies
19 positive studies were covered
2020
2021
2022
2023
2020
2021
2022
2023
11%
paxlovid 5, remdesivir 3, casirivimab/imdevimab 2, convalescent plasma 2, molnupiravir 2, one each: antiandrogens, peginterferon lambda, sargramostim, tixagevimab/cilgavimab, tocilizumab
Only 6 negative studies were covered
2020
2021
2022
2023
2020
2021
2022
2023
3%
remdesivir 3, one each: bamlanivimab/etesevimab, bebtelovimab, sotrovimab
3.8×
Positive bias for high-profit treatments
positive studies were 3.8 times more likely to be coveredFig. 24. For high-profit treatments, mainstream media coverage was biased towards positive results. When restricting to RCTs, the bias was even larger, with positive RCTs 12.0× more likely to be covered.
A combination of factors may have led to the very low media coverage of low-cost treatments:
•
Politicization
led to a media environment where coverage was often framed to support a political
narrative rather than to provide objective scientific information. As Scott Alexander
said: "if you say anything in favor of ivermectin you will be cast out
of civilization and thrown into the circle of social hell reserved for Klan members and
1/6 insurrectionists. All the health officials in the world will shout 'horse dewormer!'
at you and compare you to Josef Mengele."
There was strong social pressure to
discredit low-cost treatments.•
Censorship
of
information conflicting with selected authorities. For example, individuals and
organizations presenting conflicting science were often shadowbanned or completely banned
on Twitter and YouTube if the science they were reporting conflicted with the opinions of
specific authorities selected by those companies, including when the authorities had
not even reviewed the scientific results in question.•
FDA requires "no
adequate, approved, and available alternatives"
in order to grant an EUA for
novel high-profit interventions, creating an incentive for authorities to ignore or
downplay existing low-cost treatments.•
Regulatory
capture
biases authorities towards high-profit interventions.•
Authorities ignored
most evidence for low-cost treatments
, for example the NIH references only 2% of
studies in delayed, rarely-updated, biased commentaries with no quantitive analysis.•
Media coverage of
science is often not very accurate
, e.g., misunderstanding confounding issues. For
example the media widely considered the RECOVERY HCQ RCT to be conclusive on efficacy, but
very late treatment of late-stage patients (mostly on oxygen already) with an excessive
toxic dose (shown dangerous in a dose comparison RCT) provides no information on the
recommended early/prophylactic treatment. With difficulting in understanding basic
confounders like treatment delay and dose, the media may favor deferring to authorities.
Many studies for low-cost treatments require greater expertise to analyze.
•
Substantial funding
from pharmaceutical advertising
biases editorial decisions towards high-profit
interventions.•
PR power
-
companies/teams with strong PR presence are favored in the media, which correlates with
high-profit and high conflict of interest studies.•
The media was very
negative in general
, inflating risk, and elevating fear and anxiety. A negative bias may
improve ratings and revenue, increasing motivation to continue watching coverage.
26 low-cost treatments were approved in one
or more countries, yet many countries approved no low-cost treatments.
The countries that did adopt low-cost treatments analyzed the evidence early and made
timely approvals. With few exceptions, authorities did not change their initial views,
regardless of how much evidence accumulated showing either efficacy or harm. Why?
The harms of smoking here hidden for 25 yearsC. Authorities did not analyze the data in real-time, failing to act when
harm was known.
Widespread acknowledgement of harm came only after attempts by two new surgeon generals,
along with pressure from health advocates and a new president, and a review of 7,000 studies.
Similarly for COVID-19, most authorities and experts did not proactively
analyze data in real-time. This guarantees delayed recognition of efficacy or harm, by
which time moral, legal, career, and reputational liabilities strongly disincentivize any
admission of error. Claims of no efficacy (for effective treatments) or safety (for
harmful treatments) were often made prior to strong data being available. Correction
would require admitting to errors that increased mortality, which is unlikely with the
same generation of officials.
Analysis of potential treatments was rarely done, and when done these were
typically minimal efforts.
For example, NIH reviews were highly delayed, cover only a tiny fraction of treatments,
reference only 2% of studies for the treatments covered, and include no
quantitative analysis.
They appear as rarely updated side projects from
external panels implicitly tasked with justifying prior failures.
As with smoking, the thousands of studies could (and should)
have been analyzed and acted on in real-time.
A key structural improvement, applicable to all current and future
diseases, is for authorities to implement real-time proactive analysis of clinical
evidence. This does not remove all bias, but does make it possible to act on evidence,
whereas delayed action may be unlikely due to moral, legal, career, and reputational
liabilities.
c19early.org
Delayed public health acknowledgments
Official acknowledgment of efficacy or harm is often delayed—legal, career, and status risks disincentivize admission of error.
| Evidence | Official Acknowledgment | Approx. Delay | |
|---|---|---|---|
| Citrus Fruit (vitamin C) for Scurvy (effectiveness) | 1747: James Lind conducted one of the first-ever controlled clinical trials, proving that oranges and lemons cured scurvy in sailors. | 1795: The British Royal Navy finally made a daily ration of lemon juice a standard issue for all its sailors, effectively eliminating the disease. | 48 years |
| Handwashing (lower mortality) | 1847: Dr. Ignaz Semmelweis provided conclusive proof that having doctors wash their hands with a chlorine solution before delivering babies reduced maternal mortality rates from over 18% to around 1%. | ~1870s: Semmelweis's findings were rejected and he was ridiculed. His work was only validated decades later (after his death). | ~20+ years |
| Helicobacter pylori (bacteria causes ulcers) | 1982-1984: Marshall and Warren discovered that Helicobacter pylori bacteria causes ulcers, confirmed via direct exposure. Officials maintained that ulcers were caused by stress and spicy food. | 1994: The US NIH released a consensus statement officially recommending antibiotics as the standard treatment for peptic ulcers, overturning decades of acid-suppression therapy. | ~12 years |
| Asbestos (causes asbestosis & cancer) | 1924: The British Medical Journal published the first case study of a death from "asbestosis." By 1918, U.S. insurance companies had stopped selling life insurance to asbestos workers. | 1971 (US): The Occupational Safety and Health Administration (OSHA) was formed and began regulating asbestos as a carcinogen, setting the first federal workplace safety standards for it. | ~47 years |
| Leaded Gasoline (neurotoxicity) | ~1924: Dangers of low-level lead exposure were known. Experts like Alice Hamilton warned the U.S. Surgeon General that adding lead to gasoline would cause widespread public poisoning. | 1973 (US): The Environmental Protection Agency (EPA) ordered the first phasedown of lead in gasoline, following the Clean Air Act of 1970. A full ban for on-road vehicles took effect in 1996. | ~49 years |
| Harms of Smoking (causes lung cancer) | 1939: Franz Müller (Germany) published the first case-control epidemiological study strongly linking tobacco smoking to lung cancer. This was followed by major U.S. & U.K. studies in the 1950s. | 1964 (US): The U.S. Surgeon General's report, "Smoking and Health," was released. It was the first U.S. government report to definitively link smoking to lung cancer and heart disease. | 25 years |
Heterogeneity in COVID-19 studies arises from many factors including:
The time between infection or the onset of symptoms and
treatment may critically affect how well a treatment works. For example an
antiviral may be very effective when used early but may not be effective in
late stage disease, and may even be harmful. Oseltamivir, for example, is
generally only considered effective for influenza when used within 0-36 or
0-48 hours87,88. Baloxavir marboxil studies for influenza
also show that treatment delay is critical — Ikematsu et al. report
an 86% reduction in cases for post-exposure prophylaxis, Hayden et al.
show a 33 hour reduction in the time to alleviation of symptoms for treatment
within 24 hours and a reduction of 13 hours for treatment within 24-48 hours,
and Kumar et al. report only 2.5 hours improvement for inpatient
treatment.
Early treatment is more effective: baloxavir marboxil
November 2026
Table 3. Studies of baloxavir marboxil for influenza
show that early treatment is more effective.
Fig. 25 shows a mixed-effects meta-regression for
efficacy as a function of treatment delay in COVID-19 studies from 227 treatments, showing that efficacy
declines rapidly with treatment delay. Early treatment is critical for COVID-19.
Fig. 25. Early treatment is more effective. Meta-regression showing efficacy as a function of treatment delay in COVID-19 studies from 227 treatments.
Details of the patient population including age and comorbidities may
critically affect how well a treatment works. For example, many COVID-19
studies with relatively young low-comorbidity patients show all patients
recovering quickly with or without treatment. In such cases, there is little
room for an effective treatment to improve results, for example as in
López-Medina et al.
Efficacy may depend critically on the distribution of
SARS-CoV-2 variants encountered by patients. Risk varies significantly across
variants93, for example the Gamma variant shows significantly
different characteristics94-97. Different
mechanisms of action may be more or less effective depending on variants, for
example the degree to which TMPRSS2 contributes to viral entry can differ
across variants98,99.
Effectiveness may depend strongly on the dosage and treatment regimen.
The quality of medications may vary significantly between
manufacturers and production batches, which may significantly affect efficacy
and safety. Williams et al. analyze ivermectin from 11 different sources,
showing highly variable antiparasitic efficacy across different manufacturers.
Xu et al. analyze a treatment from two different manufacturers, showing 9
different impurities, with significantly different concentrations for each
manufacturer.
Across all
studies there is a strong association between different outcomes, for example
improved recovery is strongly associated with lower mortality. However,
efficacy may differ depending on the effect measured, for example a treatment
may be more effective against secondary complications and have minimal effect
on viral clearance.
The
distribution of studies will alter the outcome of a meta-analysis. Consider a
simplified example where everything is equal except for the treatment delay,
and effectiveness decreases to zero or below with increasing delay. If there
are many studies using very late treatment, the outcome may be negative, even
though early treatment is very effective.
All meta-analyses combine heterogeneous studies, varying in population,
variants, and potentially all factors above, and therefore may obscure
efficacy by including studies where treatment is less effective. Generally, we
expect the estimated effect size from meta-analysis to be less than that for
the optimal case.
Looking at all studies is valuable for providing an overview of all research,
important to avoid cherry-picking, and informative when a positive result is
found despite combining less-optimal situations. However, the resulting
estimate does not apply to specific cases such as
early treatment in high-risk populations.
While we present results for all studies, we also present treatment time and
individual outcome analyses, which may be more informative for specific use
cases.
This section validates the use of pooled effects for COVID-19, which enables
earlier detection of efficacy, however pooled effects are no longer required
for colchicine as of September 2020. Efficacy is now known based on specific outcomes for all studies and when restricted to RCTs.
For COVID-19, delay in clinical results translates into
additional death and morbidity, as well as additional economic and societal
damage. Combining the results of studies reporting different outcomes is
required.
There may be no mortality in a trial with low-risk patients,
however a reduction in severity or improved viral clearance may translate
into lower mortality in a high-risk population.
Different studies may report lower severity, improved recovery, and lower mortality,
and the significance may be very high when combining the results.
"The studies reported different outcomes" is not a good reason for
disregarding results.
Pooling the results of studies reporting different outcomes allows us to use
more of the available information. Logically we should, and do, use additional
information when evaluating treatments—for example dose-response and
treatment delay-response relationships provide additional evidence of efficacy
that is considered when reviewing the evidence for a treatment.
We present both specific outcome and pooled analyses.
In order to combine the results of studies reporting different outcomes we use
the most serious outcome reported in each study, based on the thesis that
improvement in the most serious outcome provides comparable measures of
efficacy for a treatment. A critical advantage of this approach is
simplicity and transparency.
There are many other ways to combine evidence for different outcomes, along
with additional evidence such as dose-response relationships, however these
increase complexity.
Trials with high-risk patients may be restricted due to ethics for treatments
that are known or expected to be effective, and they increase difficulty for
recruiting. Using less severe outcomes as a proxy for more serious outcomes
allows faster and safer collection of evidence.
For many COVID-19 treatments, a reduction in mortality logically
follows from a reduction in hospitalization, which follows from a reduction in
symptomatic cases, which follows from a reduction in PCR positivity. We can
directly test this for COVID-19.
Analysis of the the association between different outcomes across studies from
all 227
treatments we cover confirms the validity of pooled outcome analysis for COVID-19.
Fig. 26 shows that lower hospitalization is very strongly associated
with lower mortality (p < 0.0000000001).
Similarly, Fig. 27 shows that improved recovery is very strongly associated
with lower mortality (p < 0.0000000001).
Considering the extremes, Singh et al. show an association between viral clearance and
hospitalization or death, with p = 0.003 after excluding one large
outlier from a mutagenic treatment, and based on 44 RCTs including 52,384
patients.
Fig. 28 shows that improved viral clearance is strongly associated
with fewer serious outcomes. The association is very similar to
Singh et al., with higher confidence due to the larger number of
studies. As with Singh et al., the confidence increases
when excluding the outlier treatment, from p = 0.0000000074 to p = 0.00000000015.
Fig. 26. Lower hospitalization is associated with lower mortality, supporting pooled outcome analysis.
Fig. 27. Improved recovery is associated with lower mortality, supporting pooled outcome analysis.
Fig. 26. Improved viral clearance is associated with fewer serious outcomes, supporting pooled outcome analysis.
Currently, 59 of the treatments we analyze show statistically significant efficacy or harm, defined as ≥10% decreased risk or >0% increased risk from ≥3 studies. 85% of these have been confirmed with one or more specific outcomes, with a mean delay of 4.6 months. When restricting to RCTs only, 53% of treatments showing statistically significant efficacy/harm with pooled effects have been confirmed with one or more specific outcomes, with a mean delay of 7.5 months.
Fig. 29 shows when treatments were found effective during the
pandemic. Pooled outcomes often resulted in earlier detection of efficacy.
Fig. 29. The time when studies showed that
treatments were effective, defined as statistically significant improvement of
≥10% from ≥3 studies.
Pooled results typically show efficacy earlier than specific
outcome results. Results from all studies often shows efficacy much earlier
than when restricting to RCTs.
Results reflect conditions as used in trials to date, these depend on the
population treated, treatment delay, and treatment regimen.
Pooled analysis could hide efficacy, for example a treatment that is
beneficial for late stage patients but has no effect on viral clearance may
show no efficacy if most studies only examine viral clearance. In practice, it
is rare for a non-antiviral treatment to report viral clearance and to not
report clinical outcomes; and in practice other sources of heterogeneity such
as differences in treatment delay are more likely to hide efficacy.
Analysis validates the use of pooled effects and shows significantly faster
detection of efficacy on average.
However, as with all meta-analyses, it is important to review the different
studies included. We also present individual outcome analyses, which may be
more informative for specific use cases.
There are many complementary mechanisms of action for COVID-19 treatments, with
over 500 therapeutic targets55.
Studies show complementary and
synergistic effects with polytherapy102-126.
For example, Jitobaom et al.103 shows >10x reduction in
IC50 with ivermectin and niclosamide, an RCT by Said et
al.110 showed the combination of nigella sativa and vitamin D was
more effective than either alone, and an RCT by Wannigama et
al.128 showed improved results with fluvoxamine combined with
additional treatments, compared to fluvoxamine alone.
SARS-CoV-2 can rapidly acquire mutations altering infectivity,
disease severity, and drug resistance even without selective
pressure129-136.
Antigenic drift can undermine more
variant-specific treatments like monoclonal antibodies and more specific
antivirals. Treatment with targeted antivirals may select for escape
mutations137.
The efficacy of treatments varies depending on cell
type138 due to differences in viral receptor expression, drug
distribution and metabolism, and cell-specific mechanisms.
Efficacy may also vary based on genetic
variants139-149.
Variable efficacy across variants, cell types, tissues, and
host genetics, along with the complementary and synergistic actions of different
treatments, all point to greater efficacy with polytherapy.
In many studies, the standard of care given to all patients includes other
treatments—efficacy seen in these trials may rely in part on
synergistic effects.
Less variant specific treatments and polytherapy targeting multiple viral and
host proteins may be more effective.
Meta-analysis of all early treatment trials shows 71% [60‑79%] lower risk
for studies using combined treatments, compared to 27% [24‑30%] for single
treatments.
Polytherapy vs. monotherapy for all treatments
Monotherapy
Polytherapy
Early treatment
Late treatment
Prophylaxis
Studies where combined treatments may significantly contribute to efficacy are excluded from this meta-analysis150,151.
While not reaching statistical significance, colchicine studies using polytherapy also show greater efficacy than monotherapy studies.
This comparison includes combined treatment studies excluded from the rest of this paper150,151.
Polytherapy vs. monotherapy for colchicine
Monotherapy
Polytherapy
Early treatment
Late treatment
c19early.org
Combined treatment is more effective
SARS-CoV-2 involves the complex interplay of 500+ host and viral proteins and factors, providing many therapeutic targets. Many compounds have antiviral activity for SARS-CoV-2, with many different mechanisms including blocking attachment, entry, and replication. Combinations of treatments, with careful attention to potential side effects, allows improved efficacy via complementary and synergistic mechanisms.
| Tissue and cell coverage | Different compounds have different tissue penetration profiles and efficacy across cell types |
| Variant coverage | Compounds with different viral resistance profiles |
| Intra/extracellular | Disabling and removing intracellular and extracellular viral particles |
| Resistance | Minimizing persistence and emergence of resistant variants |
| Genetics | Robustness against individual variations in efficacy based on genetics |
| Lower doses | Potentially lower doses of individual agents, reducing toxicity |
| Viral and host-directed | Antivirals targeting viral and host proteins |
| Immune system function | Supporting or enhancing natural immune system function |
| Disease phases | Addressing multiple disease phases (viral replication, inflammation, secondary complications) |
Publishing is often biased
towards positive results, however evidence suggests that there may be a negative bias for
inexpensive treatments for COVID-19. Both negative and positive results are
very important for COVID-19, media in many countries prioritizes negative
results for inexpensive treatments (inverting the typical incentive for
scientists that value media recognition), and there are many reports of
difficulty publishing positive results152-155.
One method to evaluate bias is to compare prospective vs.
retrospective studies. Prospective studies are more likely to be published
regardless of the result, while retrospective studies are more likely to
exhibit bias. For example, researchers may perform preliminary analysis with
minimal effort and the results may influence their decision to continue.
Retrospective studies also provide more opportunities for the specifics of
data extraction and adjustments to influence results.
Fig. 30 shows a scatter plot of
results for prospective and retrospective studies.
50% of retrospective studies
report a statistically significant positive effect for
one or more outcomes, compared to
41% of prospective studies, consistent with a bias toward publishing positive results.
The median effect size for
retrospective studies is 23% improvement,
compared to 31% for prospective
studies, suggesting a potential bias towards publishing results showing lower efficacy.
Fig. 30. Prospective vs. retrospective studies.
The diamonds show the results of random-effects meta-analysis.
Funnel
plots have traditionally been used for analyzing publication bias. This is
invalid for COVID-19 acute treatment trials — the underlying assumptions
are invalid, which we can demonstrate with a simple example. Consider a set of
hypothetical perfect trials with no bias. Fig. 31 plot A
shows a funnel plot for a simulation of 80 perfect trials, with random group
sizes, and each patient's outcome randomly sampled (10% control event
probability, and a 30% effect size for treatment). Analysis shows no asymmetry
(p > 0.05). In plot B, we add a single typical variation in COVID-19 treatment
trials — treatment delay. Consider that efficacy varies from 90% for
treatment within 24 hours, reducing to 10% when treatment is delayed 3 days.
In plot B, each trial's treatment delay is randomly selected. Analysis now
shows highly significant asymmetry, p < 0.0001, with six variants of
Egger's test all showing p < 0.05156-163.
Note that these tests fail even though treatment delay is uniformly
distributed. In reality treatment delay is more complex — each trial has
a different distribution of delays across patients, and the distribution
across trials may be biased (e.g., late treatment trials may be more common).
Similarly, many other variations in trials may produce asymmetry, including
dose, administration, duration of treatment, differences in SOC,
comorbidities, age, variants, and bias in design, implementation, analysis,
and reporting.
Fig. 31. Example funnel plot analysis for simulated perfect trials.
Pharmaceutical drug
trials often have conflicts of interest whereby sponsors or trial staff have a
financial interest in the outcome being positive. Colchicine for COVID-19
lacks this because it is off-patent, has multiple manufacturers, and is very low cost.
In contrast, most COVID-19 colchicine trials have been run by
physicians on the front lines with the primary goal of finding the best
methods to save human lives and minimize the collateral damage caused by
COVID-19. While pharmaceutical companies are careful to run trials under
optimal conditions (for example, restricting patients to those most likely to
benefit, only including patients that can be treated soon after onset when
necessary, and ensuring accurate dosing), not all colchicine trials
represent the optimal conditions for efficacy.
Summary statistics from
meta-analysis necessarily lose information. As with all meta-analyses, studies
are heterogeneous, with differences
in treatment delay, treatment regimen, patient demographics, variants,
conflicts of interest, standard of care, and other factors. We provide analyses for specific
outcomes and by treatment delay, and we aim to identify key characteristics in
the forest plots and summaries. Results should be viewed in the context of
study characteristics.
Some analyses classify treatment based on early or late
administration, as done here, while others distinguish between mild, moderate,
and severe cases. Viral load does not indicate degree of symptoms — for
example patients may have a high viral load while being asymptomatic. With
regard to treatments that have antiviral properties, timing of treatment is
critical — late administration may be less helpful regardless of
severity.
Details of treatment delay per patient is often not available.
For example, a study may treat 90% of patients relatively early, but the
events driving the outcome may come from 10% of patients treated very late.
Our 5 day cutoff for early treatment may be too conservative, 5 days may be too late in many cases.
Comparison across treatments is confounded by differences in
the studies performed, for example dose, variants, and conflicts of interest.
Trials with conflicts of interest may use designs better suited to the
preferred outcome.
In some cases, the most serious outcome has very few events,
resulting in lower confidence results being used in pooled analysis, however
the method is simpler and more transparent. This is less critical as the
number of studies increases. Restriction to outcomes with sufficient power may
be beneficial in pooled analysis and improve accuracy when there are few
studies, however we maintain our pre-specified method to avoid any
retrospective changes.
Studies show that combinations of treatments can be highly
synergistic and may result in many times greater efficacy than individual
treatments alone102-126.
Therefore standard of care may be critical and benefits may diminish or
disappear if standard of care does not include certain treatments.
This real-time analysis is constantly updated based on
submissions. Accuracy benefits from widespread review and submission of
updates and corrections from reviewers. Less popular treatments may receive
fewer reviews.
No treatment or intervention is 100% available and
effective for all current and future variants. Efficacy may vary significantly
with different variants and within different populations. All treatments have
potential side effects. Propensity to experience side effects may be predicted
in advance by qualified physicians. We do not provide medical advice. Before
taking any medication, consult a qualified physician who can compare all
options, provide personalized advice, and provide details of risks and
benefits based on individual medical history and situations.
1 of the 54
studies compare against other treatments, which may reduce the effect
seen.
5 of 54 studies
combine treatments. The results of
colchicine
alone may differ.
4 of 30 RCTs use combined treatment.
10 other meta-analyses show significant improvements with colchicine for mortality1-8, oxygen therapy8, hospitalization9, and severity10.
SARS-CoV-2 infection and replication involves a complex
interplay of 500+ host and viral proteins and other
factors41-48, providing many therapeutic
targets.
Over 12,000 compounds have been predicted to reduce COVID-19
risk49, either by directly
minimizing infection or replication, by supporting immune system function, or
by minimizing secondary complications.
Fig. 32 shows an overview of the results for colchicine
in the context of multiple COVID-19 treatments, and Fig. 33 shows a plot
of efficacy vs. cost for COVID-19 treatments.
Fig. 33. Efficacy vs. cost for COVID-19 treatments.
Colchicine is
an effective treatment for COVID-19.
Significantly lower risk is seen for mortality, ICU admission, hospitalization, and recovery. 24 studies from 24 independent teams in 14 countries show significant
benefit.
Meta-analysis using the most serious outcome reported shows
23% [14‑31%] lower risk. Results are similar for higher quality and peer-reviewed studies and worse for Randomized Controlled Trials.
Clinical outcomes suggest benefit while viral and case outcomes do not, consistent with an intervention that aids the immune system or recovery but may have limited antiviral effects. Early treatment is more effective than late treatment.
Results are robust—in worst case exclusion sensitivity analysis 21 of 54
studies must be excluded before statistical significance is lost.
Emergent results for the efficacy gradient across outcomes (p = 0.045) that match the biological mechanisms confirm efficacy.
RCT results are less favorable, however they are dominated by the very late stage RECOVERY RCT which
is not generalizable to earlier usage.
10 other meta-analyses show significant improvements with colchicine for mortality1-8, oxygen therapy8, hospitalization9, and severity10.
Contact.
Contact us on X at @CovidAnalysis.
Funding.
We have received no funding or
compensation in any form, and do not accept donations. This is entirely volunteer work.
Conflicts of interest.
We have no conflicts of interest.
We have no affiliation with any pharmaceutical companies, supplement companies, governments, political parties, or advocacy organizations.AI.
We use AI models (Gemini, Grok, Claude, and
ChatGPT) tasked with functioning as additional peer-reviewers to check for errors, suggest
improvements, and review spelling and grammar. Any corrections are manually verified. Our preference for em dashes is independent of AI.Updates.
Our COVID-19 meta-analyses involve the extraction of over 229,000
datapoints from thousands of papers for 227 treatments. We thank the
thousands of scientists, physicians, and other contributors that have provided updates,
suggestions, feedback, and corrections. These are all welcome and can be submitted
at https://c19early.org/ometa.html.
Dedication.
This work is dedicated to top
evidence-based physicians that worked tirelessly to analyze evidence and greatly reduce
mortality and morbidity during the pandemic. In alphabetical order:
Dr. Thomas J. Borody, Dr. Mary Talley Bowden, Dr. Flavio Cadegiani, Dr. Shankara Chetty,
Dr. Ryan Cole, Dr. George Fareed, Dr. Sabine Hazan, Dr. Pierre Kory, Dr. Tess Lawrie, Dr.
Robert Malone, Dr. Paul Marik, Dr. Peter McCullough, Dr. Didier Raoult, Dr. Harvey Risch,
Dr. Jackie Stone, Dr. Brian Tyson, Dr. Joseph Varon, and Dr. Vladimir Zelenko.
Public domain.
This is a public domain work
distributed in accordance with the Creative Commons CC0 1.0 Universal license, which
dedicates the work to the public domain by waiving all rights worldwide under copyright law.
You can distribute, remix, adapt, and build upon this work in any medium or format,
including for commercial purposes, without asking permission. Referenced material and
third-party images retain any original copyrights or restrictions.
See: https://creativecommons.org/publicdomain/zero/1.0/.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in outcomes seen
Very late stage RCT with 56 colchicine and 60 control patients in Mexico, showing no significant differences.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
no CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Trial underpowered to detect differences
Small RCT 49 severe condition hospitalized patients in Syria, showing lower mortality with colchicine and shorter hospitalization time with both colchicine and budesonide (all of these were not statistically significant).
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower need for oxygen therapy with colchicine
p = 0.043
Retrospective 73 familial Mediterranean fever patients with COVID-19 in Turkey, showing significantly higher risk of hospitalization for respiratory support with non-adherence to colchicine treatment before the infection.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and higher discharge
p = 0.033 (mortality) and p = 0.033 (discharge)
PSM matched analysis from consecutive hospitalized patients, with 33 colchicine and 33 control matched patients, showing lower mortality with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower ventilation with colchicine
Not statistically significant · p = 0.29
RCT 240 hospitalized patients with COVID-19 pneumonia, mean 9 days from the onset of symptoms, showing no significant differences with colchicine treatment. EudraCT 2020-001841-38.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher mortality with colchicine
Not statistically significant · p = 0.54
Retrospective 1,213 rheumatic disease patients in France, showing no significant difference with colchicine use in univariate analysis.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Study underpowered for serious outcomes
Retrospective 244 Behçet disease patients in Spain, showing no significant difference in outcomes with colchicine treatment. Confounding by indication may significantly affect results - colchicine may be prescribed more often for more serious cases, which may have a higher baseline risk for COVID-19.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower progression with colchicine
p = 0.046
RCT with 55 patients treated with colchicine and 50 control patients, showing lower mortality and ventilation with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and death/intubation
Not statistically significant · p = 0.3 (mortality) and p = 0.08 (death/intubation)
Very late stage RCT (O2 88%, 84% on oxygen) with 1,279 hospitalized patients in Argentina, showing lower mortality and lower combined mortality/ventilation, statistically significant only for the combined outcome and per-protocol analysis. NCT04328480. COLCOVID.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
Not statistically significant · p = 0.43
Late treatment RCT with 156 colchicine patients in the UK, showing no significant differences.
c19early.org
PRINCIPLE trial selective reporting delays
Results for effective but politically inconvenient treatments were withheld for very long periods.
| Treatment patients | Duration | Results delay | |
|---|---|---|---|
| HCQ240 | 413 | 2 months | Over 5 years240 |
| Azithromycin241 | 540 | 6 months | 56 days242 |
| Budesonide243 | 1,073 | 4 months | 12 days244 |
| Doxycycline245 | 780 | 5 months | 42 days242 |
| Colchicine187 | 156 | 3 months | 120 days246 |
| Ivermectin51 | 2,157 | 14 months | 600 days (810 days from ~1,000 per arm enrollment) |
| Favipiravir247 | ~2,250 | 15 months | 780 days (1,000 days from ~1,000 per arm enrollment) |
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in outcomes seen
Late (5.4 days) outpatient RCT showing no significant difference in outcomes with colchicine treatment. Authors include a meta analysis of 6 colchicine RCTs, however there were 19 RCTs as of the publication date248.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in outcomes seen
RCT very late stage (baseline SpO2 80%) patients, showing no significant differences with colchicine treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with treatment
Not statistically significant · p = 0.38
RCT 633 hospitalized patients in Colombia, 153 treated with colchicine + rosuvastatin, 160 treated with emtricitabine + tenofovir, and 159 treated with the combination of both regimens. Statistically significant improvement was seen only for the combination of emtricitabine + tenofovir + rosuvastatin + colchicine.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower ICU admission and improved recovery
Not statistically significant · p = 0.11 (ICU admission) and p = 0.14 (recovery)
Open-label RCT 137 hospitalized COVID-19 patients, showing lower progression to ICU/step-down ICU and improved recovery with colchicine, both without statistical significance. The primary outcome was changed mid-trial due to the low number of patients progressing to severe disease.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Improved recovery with colchicine
p = 0.001
RCT with 80 colchicine and 80 control patients, showing improved recovery with treatment. SOC included vitamin C, vitamin D, and zinc.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Improved recovery with colchicine
Not statistically significant · p = 0.11
Open-label RCT 96 hospitalized COVID-19 patients in Pakistan showing no significant difference in clinical outcomes with colchicine treatment, however baseline severity was not comparable - 85% vs. 56% had SpO2 <93 (p = 0.003), with the Q3 SpO2 in the treatment group less than the median value in the control group. The only adjusted results are for recovery, where the Fine-Gray model is likely more appropriate (it directly models the cumulative probability of recovery and discharge, which was the primary endpoint of interest, better handles competing risks in a way that's more clinically interpretable for the probability a patient will be discharged alive, and is particularly useful when the focus is on the absolute risk of an event rather than the rate at which events occur among those still at risk).
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
no CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Trial underpowered for serious outcomes
RCT 150 patients in Egypt showing no significant difference in outcomes with colchicine. SOC included vitamin C, D, and zinc. Colchicine 0.5mg tid days 1-3, bid days 4-7.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher ventilation with colchicine
Not statistically significant · p = 0.06
RCT with 5,610 colchicine and 5,730 control patients showing mortality RR 1.01 [0.93-1.10]. Very late stage treatment, median 9 days after symptom onset, baseline 32% ventilation (5% invasive). ISRCTN 50189673. 6-month results are from Horby (B) et al.
Dose frequency was halved for patients receiving a moderate CYP3A4 inhibitor, patients with an estimated glomerular filtration rate of less than 30 mL/min per 1·73m², and those with an estimated bodyweight of less than 70kg.
Dose frequency was halved for patients receiving a moderate CYP3A4 inhibitor, patients with an estimated glomerular filtration rate of less than 30 mL/min per 1·73m², and those with an estimated bodyweight of less than 70kg.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher mortality with colchicine
Not statistically significant · p = 0.33
Retrospective 200 patients with ARDS due to COVID-19 on invasive mechanical ventilation, showing no significant difference in mortality with colchicine treatment. The Cox proportional hazards result is from250.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.025
Retrospective 450 late stage (median oxygen saturation 86%) COVID+ hospitalized patients in Peru, showing lower mortality with colchicine treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.0029
Retrospective 26,508 consecutive COVID+ veterans in the USA, showing lower mortality with multiple treatments including colchicine. Treatment was defined as drugs administered ≥50% of the time within 2 weeks post-COVID+, and may be a continuation of prophylactic treatment in some cases, and may be early or late treatment in other cases. Further reduction in mortality was seen with combinations of treatments.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower hospitalization with treatment
Not statistically significant · p = 0.55
Trial compares with loxoprofen, results vs. placebo may differ
RCT 38 low risk outpatients in Japan, showing no significant differences for colchicine and low-dose aspirin compared to loxoprofen. Hospitalization was lower, without statistical significance (4.3% vs. 13.3%, p=0.34). There were no critical cases, deaths, or severe adverse events in either group.
Colchicine: 1.0mg loading dose, followed approximately half a day later by 0.5mg twice daily for 10 doses, and then 0.5 mg once daily for four doses. Aspirin: 100mg daily for 10 days. Both groups received probiotics and acetaminophen.
Colchicine: 1.0mg loading dose, followed approximately half a day later by 0.5mg twice daily for 10 doses, and then 0.5 mg once daily for four doses. Aspirin: 100mg daily for 10 days. Both groups received probiotics and acetaminophen.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Shorter hospitalization with colchicine
p = 0.009
Open label RCT of colchicine showing improved recovery with treatment. Only the abstract is currently available. Colchicine 0.5mg bid for 14 days.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Shorter hospitalization with colchicine
p = 0.0001
Retrospective 356 hospitalized COVID-19 patients, shorter hospitalization time with colchicine treatment. There were no statistically significant differences for mortality or ICU admission. Significantly lower mortality was seen with higher dosage (1mg/day vs 0.5mg/day). More control patients were on oxygen at baseline (65% vs. 54%).
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Improved recovery with colchicine
Not statistically significant · p = 0.59
Very late treatment (10 days from onset) RCT 110 patients in Iran, showing no significant difference in outcomes with colchicine. Colchicine 2mg loading dose followed by 0.5mg bid for 7 days.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in outcomes seen
Early terminated RCT with 14 colchicine, 13 edoxaban, 16 colchicine+edoxaban, and 16 control patients, showing no significant difference in outcomes with treatment up to 7 days after PCR diagnosis.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Shorter hospitalization with colchicine
p = 0.01
RCT with 36 colchicine and 36 control patients, showing reduced length of hospitalization and oxygen therapy with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher mortality and hospitalization
Not statistically significant · p = 0.57 (mortality) and p = 0.2 (hospitalization)
Retrospective 9,379 patients attending a rheumatology outpatient clinic in Spain, showing higher mortality and hospitalization with colchicine use, without statistical significance.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Study underpowered to detect differences
Retrospective 134 hospitalized COVID-19 patients in India, showing no significant difference with colchicine treatment in unadjusted results.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.0054
IPTW retrospective 141 COVID-19 patients (83% hospitalized), 71 treated with colchicine and 70 matched control patients, showing lower mortality and faster recovery with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and improved recovery
Not statistically significant · p = 0.49 (mortality) and p = 0.064 (recovery)
Small trial with 21 colchicine patients and 22 control patients in Russia, showing improved recovery with treatment. The trial was originally an RCT, however randomization to the control arm was stopped after 5 patients, and 17 retrospective patients were added for comparison.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher mortality with colchicine
p = 0.0000011
Retrospective study of 917,198 hospitalized COVID-19 cases covered by the Iran Health Insurance Organization over 26 months showing that antithrombotics, corticosteroids, and antivirals reduced mortality while diuretics, antibiotics, and antidiabetics increased it. Confounding makes some results very unreliable. For example, diuretics like furosemide are often used to treat fluid overload, which is more likely in ICU or advanced disease requiring aggressive fluid resuscitation. Hospitalization length has increased risk of significant confounding, for example longer hospitalization increases the chance of receiving a medication, and death may result in shorter hospitalization. Mortality results may be more reliable.
Confounding by indication is likely to be significant for many medications. Authors adjustments have very limited severity information (admission type refers to ward vs. ER department on initial arrival). We can estimate the impact of confounding from typical usage patterns, the prescription frequency, and attenuation or increase of risk for ICU vs. all patients.
Confounding by indication is likely to be significant for many medications. Authors adjustments have very limited severity information (admission type refers to ward vs. ER department on initial arrival). We can estimate the impact of confounding from typical usage patterns, the prescription frequency, and attenuation or increase of risk for ICU vs. all patients.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.022
PSM retrospective 3,712 hospitalized patients in Spain, showing lower mortality with existing use of azithromycin, bemiparine, budesonide-formoterol fumarate, cefuroxime, colchicine, enoxaparin, ipratropium bromide, loratadine, mepyramine theophylline acetate, oral rehydration salts, and salbutamol sulphate, and higher mortality with acetylsalicylic acid, digoxin, folic acid, mirtazapine, linagliptin, enalapril, atorvastatin, and allopurinol.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in cases
Prospective analysis of 1,047 Behçet’s syndrome patients in Turkey, showing no significant difference in cases with colchicine use.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher hospitalization and more symptomatic cases
Not statistically significant · p = 0.12 (hospitalization) and p = 0.072 (more symptomatic cases)
Retrospective 635 HCQ users and 643 household contacts, showing higher risk with colchicine in unadjusted results.
Patients with conditions leading to the use of colchicine may have significantly different baseline risk, e.g.205.
Patients with conditions leading to the use of colchicine may have significantly different baseline risk, e.g.205.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Improved 7-point scale results with colchicine
p = 0.03
RCT with 52 colchicine patients and 51 control patients, showing lower risk of clinical deterioration with treatment. COL-COVID. NCT04350320.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower ICU admission with colchicine
Not statistically significant · p = 0.21
RCT 152 hospitalized patients in Italy, showing no significant difference in outcomes with colchicine treatment. Table 2 shows 13% of patients treated with antivirals in the colchicine arm, however 16.9% were treated with one specific antiviral (HCQ).
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and greater improvement
Not statistically significant · p = 0.49 (mortality) and p = 0.23 (improvement)
Open label RCT late stage hospitalized patients in Brazil with 14 colchicine and 16 SOC patients, showing lower mortality and improved recovery with treatment, without statistical significance. Authors note that the colchicine group had one patient with SOFA ≥7 vs. zero for SOC, however both groups had one patient intubated and SOC had more patients not requiring high-flow oxygen (12 vs. 8).
The journal version of this paper incorrectly states: "Ixekizumab, colchicine, and IL-2 were demonstrated to be safe but ineffective". The pre-print more accurately represents the improved but not statistically significant results:
"The colchicine arm presented the lowest mortality rate (0%), while the low dose IL-2 had the highest (21.4%) by day 28 post-enrollment. The frequency of adverse events was lowest in the colchicine group (7.3%). None of the differences observed was statistically significant. Interpretation: Colchicine added to SOC performed better than Ixekizumab, low-dose IL-2, or SOC alone for hospitalized patients with moderate to critical Covid-19 in this exploratory study. Larger studies are needed to confirm these findings."
The journal version of this paper incorrectly states: "Ixekizumab, colchicine, and IL-2 were demonstrated to be safe but ineffective". The pre-print more accurately represents the improved but not statistically significant results:
"The colchicine arm presented the lowest mortality rate (0%), while the low dose IL-2 had the highest (21.4%) by day 28 post-enrollment. The frequency of adverse events was lowest in the colchicine group (7.3%). None of the differences observed was statistically significant. Interpretation: Colchicine added to SOC performed better than Ixekizumab, low-dose IL-2, or SOC alone for hospitalized patients with moderate to critical Covid-19 in this exploratory study. Larger studies are needed to confirm these findings."
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
Not statistically significant · p = 0.18
Retrospective 301 pneumonia patients in Colombia showing lower mortality with colchicine treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower hospitalization and improved recovery
p = 0.0037 (hospitalization) and p = 0.025 (recovery)
RCT 202 patients in Iran, 102 treated with colchicine, showing lower hospitalization and improved clinical outcomes with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and progression
p = 0.035 (mortality) and p = 0.035 (progression)
RCT 300 patients in Bangladesh, published 2 years after completion, showing significantly lower mortality with treatment at 28 days (not significant at 14 days). 1.2mg colchicine on day 1 followed by 0.6mg for 13 days.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in mortality
Retrospective 313 patients, mostly critical stage and mostly requiring respiratory support. Confounding by indication likely.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Shorter hospitalization with colchicine
p = 0.001
Open label RCT with 100 hospitalized patients in Iran, 50 treated with colchicine, showing shorter hospitalization time with treatment. There were no deaths.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
no CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and ventilation
p = 0.0006 (mortality) and p < 0.0001 (ventilation)
Prospective cohort study of hospitalized patients in the USA, 34 treated with colchicine, showing lower mortality and intubation with treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.000038
Retrospective 122 colchicine patients and 140 control patients in Italy, showing lower mortality with treatment.
Confounding may be significant: the groups were recruited during different time periods of a rapidly evolving epidemic - the control group during the chaotic peak of Lombardy's COVID crisis (March 5 - 19, 2020) when hospitals were overwhelmed and clinical protocols were still being developed, versus the treatment group later (March 19 - April 5) when care had improved.
Confounding may be significant: the groups were recruited during different time periods of a rapidly evolving epidemic - the control group during the chaotic peak of Lombardy's COVID crisis (March 5 - 19, 2020) when hospitals were overwhelmed and clinical protocols were still being developed, versus the treatment group later (March 19 - April 5) when care had improved.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Higher mortality and ventilation
Not statistically significant · p = 0.54 (mortality) and p = 0.28 (ventilation)
RCT 250 late stage (80% on oxygen) hospitalized patients in the USA, showing no significant differences with combined colchicine/rosuvastatin treatment.
There was a trend towards increased risk, which authors note may be due to chance because the patients enrolled in the treatment arm were in more serious condition, for example, patients in the treatment arm were more frequently on oxygen, more frequently on HFNC/NIV, and had higher mean SOFA scores.
Colchicine 0.6mg two times daily for 3 days followed by 0.6mg daily, and high-intensity rosuvastatin 40mg daily.
There was a trend towards increased risk, which authors note may be due to chance because the patients enrolled in the treatment arm were in more serious condition, for example, patients in the treatment arm were more frequently on oxygen, more frequently on HFNC/NIV, and had higher mean SOFA scores.
Colchicine 0.6mg two times daily for 3 days followed by 0.6mg daily, and high-intensity rosuvastatin 40mg daily.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Trial underpowered for serious outcomes
RCT 122 hospitalized patients in India, showing improved recovery with colchicine treatment. All patients received aspirin. There was one death and higher progression in the colchicine arm, however 3 patients in the colchicine arm had baseline ordinal scores ≥5, while no patients in the control arm did.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
No significant difference in outcomes seen
Retrospective 86,652 patients in Spain, showing no significant difference in cases and hospitalization with colchicine use. The different risk for patients prescribed colchicine may not be fully adjusted for. See251.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and death/hosp.
Not statistically significant · p = 0.3 (mortality) and p = 0.079 (death/hosp.)
RCT for relatively low risk outpatients, 2235 treated with colchicine a mean of 5.3 days after the onset of symptoms, and 2253 controls, showing lower mortality, ventilation, and hospitalization with treatment.
This study was submitted to NEJM which delayed for ~6 months and then said they were not interested, then to JAMA which delayed for ~6 months and then said they were not interested, and then to the Lancet which delayed for ~6 months and then said they were not interested, and finally was published in Lancet Respiratory Medicine252.
This study was submitted to NEJM which delayed for ~6 months and then said they were not interested, then to JAMA which delayed for ~6 months and then said they were not interested, and then to the Lancet which delayed for ~6 months and then said they were not interested, and finally was published in Lancet Respiratory Medicine252.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
Not statistically significant · p = 0.12
UK Biobank retrospective showing a higher risk of COVID-19 cases and mortality for patients with gout. Among patients with gout, mortality risk was lower for those on colchicine, OR 1.06 [0.60-1.89], compared to those without colchicine, OR 1.38 [1.08-1.76].
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Shorter ICU admission with treatment
p = 0.03
Retrospective 65 ICU patients in the USA and Honduras, showing shorter ICU stay with combined treatment including colchicine, LMWH, tocilizumab, dexamethasone, and methylprednisolone.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality and ICU admission
p = 0.03 (mortality) and p = 0.0019 (ICU admission)
RCT 179 hospitalized COVID-19 patients showing lower mortality, ICU admission, and hospitalization duration with colchicine plus phenolic monoterpenes compared to standard care alone. The intervention group received 0.8 mg/day colchicine and 45 mg/day phenolic monoterpenes extracted from nigella sativa and Trachyspermum ammi in addition to standard care (lopinavir/ritonavir). No serious side effects were reported. Baseline SpO2 was significantly lower in the control group, although there was no significant difference in severity according to NIH guidelines.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
p = 0.031
Retrospective 111 hospitalized COVID-19 pneumonia patients treated with colchicine and 111 matched controls, showing lower mortality with colchicine treatment.
Colchicine for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Colchicine
reduces riskColchicine
increases risk →
reduces riskColchicine
increases risk →
Lower mortality with colchicine
Not statistically significant · p = 0.54
Open-label RCT with 52 severe COVID-19 pneumonia patients showing no significant differences in mortality with colchicine. All patients received infliximab and remdesivir.
We perform ongoing searches of PubMed, medRxiv, Europe PMC, ClinicalTrials.gov, The Cochrane
Library, Google Scholar, Research Square, ScienceDirect, Oxford University Press, the
reference lists of other studies and meta-analyses, and submissions to the site c19early.org, which regularly receives notification of studies upon
publication.
Search terms are colchicine and COVID-19 or SARS-CoV-2. Automated searches are performed twice daily, with all matches reviewed for inclusion.
All studies regarding the use of colchicine for COVID-19 that report a comparison with a
control group are included in the main analysis.
Sensitivity analysis is performed, excluding studies with major issues, epidemiological
studies, and studies with minimal available information.
Studies with major unexplained data issues, for example major outcome data that is
impossible to be correct with no response from the authors, are excluded.

Fig. 34.
Mid-recovery results can more accurately reflect efficacy when almost all patients
recover. Mateja et al. confirm that intermediate viral load results more accurately
reflect hospitalization/death.
We extracted effect sizes and associated data from all studies. If studies report multiple
kinds of effects then the most serious outcome is used in pooled analysis, while
other outcomes are included in the outcome-specific analyses. For example, if effects for
mortality and cases are reported then they are both used in specific outcome analyses,
while mortality is used for pooled analysis.
If symptomatic results are reported at multiple times, we use the latest time, for example
if mortality results are provided at 14 days and 28 days, the results at 28 days have
preference. Mortality alone is preferred over combined outcomes.
Outcomes with zero events in both arms are not used, the next most serious outcome with
one or more events is used. For example, in low-risk populations with no mortality, a
reduction in mortality with treatment is not possible, however a reduction in
hospitalization, for example, is still valuable.
Clinical outcomes are considered more important than viral outcomes.
When basically all patients recover in both treatment and control groups, preference for
viral clearance and recovery is given to results mid-recovery where available. After most
or all patients have recovered there is little or no room for an effective treatment to do
better, however faster recovery is valuable.
An IPD meta-analysis confirms that intermediate viral load reduction is more closely
associated with hospitalization/death than later viral load reduction253.
If only individual symptom data is available, the most serious symptom has
priority, for example difficulty breathing or low SpO2 is more
important than cough.
Forest plots are computed using PythonMeta254 with the DerSimonian and
Laird random-effects model (the fixed effect assumption is not plausible in this case) and
inverse variance weighting.
Results are presented with 95% confidence intervals. Heterogeneity among studies was
assessed using the I2 statistic.
When results provide an odds ratio, we compute the relative risk when possible, or convert
to a relative risk according to Zhang et al.
Reported confidence intervals and p-values are used when available, and adjusted
values are used when provided. If multiple types of adjustments are reported propensity
score matching and multivariable regression has preference over propensity score matching
or weighting, which has preference over multivariable regression. Adjusted results have
preference over unadjusted results for a more serious outcome when the adjustments
significantly alter results.
When needed, conversion between reported p-values and confidence intervals followed
Altman, Altman (B), and Fisher's exact test was used to calculate
p-values for event data. If continuity correction for zero values is required, we
use the reciprocal of the opposite arm with the sum of the correction factors equal to
1258.
Results are expressed with RR < 1.0 favoring treatment, and using the risk of a negative
outcome when applicable (for example, the risk of death rather than the risk of survival).
If studies only report relative continuous values such as relative times, the ratio of the
time for the treatment group versus the time for the control group is used. Calculations
are done in Python (3.15.2) with
scipy (1.18.1), pythonmeta (1.26), numpy (2.5.4), statsmodels (0.15.0), and plotly (6.9.0).
Mixed-effects meta-regression results are computed with R (4.4.0) using the metafor
(4.6-0) and rms (6.8-0) packages, and using the most serious sufficiently powered outcome.
For all statistical tests, a p-value less than 0.05 was considered statistically
significant.
Grobid 0.8.2 is used to parse PDF documents.
For treatments that are predicted to have potential benefits later in infection rather than
via a direct antiviral effect,
we may expect a gradient of efficacy across outcomes,
with minimal impact on preventing initial infection (PCR+ cases), but increasing efficacy
against more severe outcomes. To evaluate this hypothesis we performed meta-regression
with robust variance estimation. Clinical outcomes were categorized into an ordinal
severity scale with cases at severity 1, hospitalization at severity 2, and critical
outcomes at severity 3 (ICU admission, ventilation, and mortality).
The dependent variable was the natural logarithm of the Risk Ratio (ln(RR)) for each
outcome, and the independent variable was the ordinal severity score.
We used the DerSimonian and Laird (DL) method-of-moments estimator to estimate residual
heterogeneity (τ2) around the meta-regression line, with weights assigned
using the inverse-variance method (wi = 1 / (vi +
τ2)).
To account for the non-independence of multiple outcomes reported within the same study
(e.g., mortality and hospitalization data derived from the same patient population), we
used cluster-robust standard errors clustered by study ID.
The meta-regression slope (β) represents the change in ln(RR) per unit
increase in severity. A negative slope indicates improving efficacy (lower Risk
Ratio) for more severe outcomes.
When evaluating potential effect modification across groups, we use an
interaction test as described by Altman (C) et al. We compared the log-transformed
relative risks using a z-test, deriving the standard error of the difference from
the 95% confidence intervals. A two-sided interaction p-value of < 0.05 was
considered a statistically significant difference in treatment effect between the
groups.
Cochrane RoB 2/ROBINS-I are often used to evaluate studies, and have the advantage of
providing standardized rules that can be applied with minimal understanding of the domain
and study. However, the rules do not account for many real-world issues, often
overemphasize or underemphasize others, and studies show low inter-rater
reliability266.
Certain domains are more applicable for these tools, however the time-sensitive nature of
a pandemic, with significant mortality for every day of delay in evidence assessment, and
the characteristics of COVID-19 make them inappropriate for this domain.
This can be demonstrated with examples where expert RoB 2/ROBINS-I ratings do not match
reality for COVID-19. Popp et al. use RoB 2 to classify Reis et al. as low
risk of bias, however this is the opposite of reality—the trial not only has very
high risk of bias, but has very high actual known bias, refusing to release data despite
pledging to, reporting multiple impossible numbers, having blinding and randomization
failure, and many other issues268.
Axfors et al. use RoB 2 to classify Horby (C) et al. as low risk of bias, however
this is the opposite of reality—the very late treatment and excessive dosage used
produces results with no relevance to recommended usage.
HCQ shows poor results with
late treatment and excessive dosage, and the combination shows harmD.
Hempenius et al. use ROBINS-I to classify 33 studies for HCQ. The two rated as having
the lowest risk of bias264,265 are far from the most informative. Both
involve very late treatment, providing no information on recommended usage, and ROBINS-I
does a very poor job of accounting for the impact of confounding factorsE.
Our quality evaluation focuses on known issues and bias, and the potential
impact on outcomes, rather than just the risk of bias.
The estimated potential impact of each confounding factor, and the direction of the impact
is considered. For example, consider a study that shows significantly lower risk, the
value of the study varies significantly if confounding points to an underestimate or an
overestimate of efficacy. In one case, the real effect may be null, while the other case
provides stronger evidence of efficacy (which may be greater than the study shows).
Analysis focusing on the risk of bias, while simpler, may penalize studies for theoretical
or technical issues that have no or minimal impact on outcomes. Analysis also depends on
the outcome, for example certain issues are less relevant for objective outcomes such as
mortality.
Inaccurate penalization, and inaccurate high-quality evaluation in the face of known major
issues affecting outcomes, increases in significance during a pandemic when immediate
recognition of new evidence is critical, and when considering all global studies, as
required during a pandemic. Investigators in other countries may have different customs
for design, analysis, and reporting, and different English language skills, however they
may not be less diligent or have greater bias.
Investigators in lower-pharmaceutical-profit countries may have lower bias towards
profitable interventions.
We have classified studies as
early treatment if most patients are not already at a severe stage at the time of
treatment (for example based on oxygen status or lung involvement), and treatment started
within 5 days of the onset of symptoms. If studies contain a mix of early treatment and
late treatment patients, we consider the treatment time of patients contributing most to
the events (for example, consider a study where most patients are treated early but late
treatment patients are included, and all mortality events were observed with late
treatment patients).
We note that a shorter time may be preferable. Antivirals are typically only considered
effective when used within a shorter timeframe, for example 0-36 or 0-48 hours for
oseltamivir, with longer delays not being effective87,88.
This is a living analysis and is updated regularly.
We received no funding, this research is done in our spare time.
We have no affiliation with any pharmaceutical companies, supplement companies, governments, political parties, or advocacy organizations.
A summary of study results is below. Please submit
updates and corrections at https://c19early.org/ometa.html.
Effect extraction follows pre-specified rules as detailed above
and gives priority to more serious outcomes.
For pooled analyses, the first (most serious) outcome is used, which may
differ from the effect a paper focuses on.
Other outcomes are used in outcome specific analyses.
| Hassan, 6/13/2023, Randomized Controlled Trial, Egypt, preprint, 6 authors, study period July 2021 - August 2022. | risk of hospitalization, 40.0% higher, RR 1.40, p = 0.76, treatment 7 of 50 (14.0%), control 5 of 50 (10.0%). |
| risk of no recovery, 3.6% lower, RR 0.96, p = 1.00, treatment 27 of 50 (54.0%), control 28 of 50 (56.0%), NNT 50. | |
| Hunt, 6/29/2022, retrospective, USA, peer-reviewed, 8 authors, study period 1 March, 2020 - 10 September, 2020, dosage not specified. | risk of death, 68.0% lower, RR 0.32, p = 0.003, treatment 9 of 402 (2.2%), control 1,603 of 26,106 (6.1%), NNT 26, adjusted per study, day 30. |
| Inokuchi, 3/19/2024, Randomized Controlled Trial, Japan, peer-reviewed, 16 authors, study period 27 July, 2021 - 6 September, 2021, average treatment delay 1.8 days, this trial compares with another treatment - results may be better when compared to placebo, this trial uses multiple treatments in the treatment arm (combined with aspirin) - results of individual treatments may vary. | risk of hospitalization, 67.4% lower, RR 0.33, p = 0.55, treatment 1 of 23 (4.3%), control 2 of 15 (13.3%), NNT 11, day 28. |
| prolonged symptoms, 23.8% lower, RR 0.76, p = 0.72, treatment 8 of 21 (38.1%), control 6 of 12 (50.0%), NNT 8.4. | |
| days until ≤37°C, 17.0% higher, relative time 1.17, p = 0.60, treatment 21, control 12. |
Effect extraction follows pre-specified rules as detailed above
and gives priority to more serious outcomes.
For pooled analyses, the first (most serious) outcome is used, which may
differ from the effect a paper focuses on.
Other outcomes are used in outcome specific analyses.
| Absalón-Aguilar, 11/9/2021, Double Blind Randomized Controlled Trial, placebo-controlled, Mexico, peer-reviewed, 18 authors, study period May 2020 - April 2021, dosage 1.5mg day 1, 1mg days 2-10. | risk of death, 28.6% lower, RR 0.71, p = 0.74, treatment 4 of 56 (7.1%), control 6 of 60 (10.0%), NNT 35. |
| progression to critical or death, 17.0% lower, OR 0.83, p = 0.67, treatment 56, control 60, primary outcome, RR approximated with OR. | |
| risk of no recovery, 13.0% higher, RR 1.13, p = 0.59, treatment 56, control 60, Kaplan-Meier. | |
| Alsultan, 12/31/2021, Randomized Controlled Trial, Syria, peer-reviewed, 11 authors, dosage 2mg day 1, 1mg days 2-5. | risk of death, 35.7% lower, RR 0.64, p = 0.70, treatment 3 of 14 (21.4%), control 7 of 21 (33.3%), NNT 8.4. |
| Brunetti, 9/14/2020, retrospective, propensity score matching, USA, peer-reviewed, baseline oxygen required 86.4%, 7 authors, dosage 1.2mg daily. | risk of death, 72.7% lower, RR 0.27, p = 0.03, treatment 3 of 33 (9.1%), control 11 of 33 (33.3%), NNT 4.1, PSM. |
| risk of no hospital discharge, 72.7% lower, RR 0.27, p = 0.03, treatment 3 of 33 (9.1%), control 11 of 33 (33.3%), NNT 4.1, PSM. | |
| Cecconi, 6/2/2022, Double Blind Randomized Controlled Trial, placebo-controlled, Spain, peer-reviewed, mean age 65.0, 31 authors, study period August 2020 - March 2021, average treatment delay 9.0 days, dosage 1mg day 1, 0.5mg days 2-5. | risk of death, 29.4% lower, RR 0.71, p = 0.62, treatment 7 of 119 (5.9%), control 10 of 120 (8.3%), NNT 41. |
| risk of mechanical ventilation, 49.6% lower, RR 0.50, p = 0.29, treatment 5 of 119 (4.2%), control 10 of 120 (8.3%), NNT 24. | |
| risk of ICU admission, 20.8% lower, RR 0.79, p = 0.67, treatment 11 of 119 (9.2%), control 14 of 120 (11.7%), NNT 41. | |
| combined NIV/ICU/ventilation/death, 15.3% lower, RR 0.85, p = 0.62, treatment 21 of 119 (17.6%), control 25 of 120 (20.8%), NNT 31, primary outcome. | |
| Deftereos, 6/24/2020, Randomized Controlled Trial, Greece, peer-reviewed, baseline oxygen required 62.9%, 49 authors, study period 3 April, 2020 - 27 April, 2020, dosage 2mg day 1, 1mg days 2-21, trial NCT04326790 (history) (GRECCO-19). | risk of death, 77.3% lower, RR 0.23, p = 0.19, treatment 1 of 55 (1.8%), control 4 of 50 (8.0%), NNT 16. |
| risk of mechanical ventilation, 81.8% lower, RR 0.18, p = 0.10, treatment 1 of 55 (1.8%), control 5 of 50 (10.0%), NNT 12. | |
| risk of clinical deterioration, 87.4% lower, RR 0.13, p = 0.046, treatment 1 of 55 (1.8%), control 7 of 50 (14.0%), NNT 8.2, odds ratio converted to relative risk. | |
| Diaz, 12/29/2021, Randomized Controlled Trial, Argentina, peer-reviewed, 101 authors, study period 17 April, 2020 - 28 March, 2021, dosage 2mg day 1, 1mg days 2-14, trial NCT04328480 (history), excluded in exclusion analyses: very late stage, oxygen saturation <90% at baseline; very late stage, >80% on oxygen/ventilation at baseline. | risk of death, 12.0% lower, HR 0.88, p = 0.30, treatment 131 of 640 (20.5%), control 142 of 639 (22.2%), NNT 57, adjusted per study, Cox proportional hazards, primary outcome. |
| risk of death/intubation, 17.0% lower, HR 0.83, p = 0.08, treatment 160 of 640 (25.0%), control 184 of 639 (28.8%), NNT 26, adjusted per study, Cox proportional hazards, primary outcome. | |
| risk of death/intubation, 52.0% lower, HR 0.48, p = 0.60, treatment 6 of 93 (6.5%), control 13 of 102 (12.7%), NNT 16, adjusted per study, subset not on supplemental oxygen, Cox proportional hazards. | |
| risk of death, 17.0% lower, HR 0.83, p = 0.30, treatment 98 of 515 (19.0%), control 140 of 634 (22.1%), NNT 33, adjusted per study, PP, Cox proportional hazards. | |
| risk of death/intubation, 25.0% lower, HR 0.75, p = 0.02, treatment 117 of 515 (22.7%), control 181 of 634 (28.5%), NNT 17, adjusted per study, PP, Cox proportional hazards. | |
| Dorward, 9/23/2021, Randomized Controlled Trial, United Kingdom, peer-reviewed, 21 authors, study period 4 March, 2021 - 26 May, 2021, average treatment delay 6.0 days, dosage 0.5mg days 1-14, trial ISRCTN86534580 (PRINCIPLE). | risk of death, 69.7% lower, RR 0.30, p = 0.43, treatment 0 of 156 (0.0%), control 1 of 120 (0.8%), NNT 120, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| risk of death/hospitalization, 29.8% higher, RR 1.30, p = 0.66, treatment 6 of 156 (3.8%), control 4 of 133 (3.0%), odds ratio converted to relative risk, concurrent randomisation. | |
| risk of death/hospitalization, 22.1% lower, RR 0.78, p = 0.59, treatment 6 of 156 (3.8%), control 119 of 1,145 (10.4%), odds ratio converted to relative risk, including control patients before the colchicine arm started. | |
| risk of no recovery, 6.4% higher, HR 1.06, p = 0.67, treatment 156, control 133, inverted to make HR<1 favor treatment, time to alleviation of symptoms, concurrent randomisation. | |
| Eikelboom (B), 10/10/2022, Randomized Controlled Trial, Canada, peer-reviewed, mean age 45.0, 31 authors, study period 27 August, 2020 - 10 February, 2022, average treatment delay 5.4 days, dosage 1.2mg days 1-3, 0.6mg days 4-28, trial NCT04324463 (history) (ACT outpatient). | risk of death, 9.0% higher, HR 1.09, p = 0.84, treatment 12 of 1,939 (0.6%), control 11 of 1,942 (0.6%). |
| risk of death/hospitalization, 2.0% higher, HR 1.02, p = 0.93, treatment 66 of 1,939 (3.4%), control 65 of 1,942 (3.3%), primary outcome. | |
| risk of hospitalization, 2.0% higher, HR 1.02, p = 0.92, treatment 62 of 1,939 (3.2%), control 61 of 1,942 (3.1%). | |
| Eikelboom, 10/10/2022, Randomized Controlled Trial, multiple countries, peer-reviewed, mean age 56.0, 29 authors, study period 2 October, 2020 - 10 February, 2022, average treatment delay 7.0 days, dosage 1.8mg day 1, 1.2mg days 2-28, trial NCT04324463 (history) (ACT inpatient), excluded in exclusion analyses: very late stage, oxygen saturation <90% at baseline. | risk of death, 8.0% higher, HR 1.08, p = 0.38, treatment 264 of 1,304 (20.2%), control 249 of 1,307 (19.1%). |
| risk of progression, 4.0% higher, HR 1.04, p = 0.58, treatment 368 of 1,304 (28.2%), control 356 of 1,307 (27.2%), high-flow oxygen, ventilation, or death. | |
| risk of progression, 2.0% lower, HR 0.98, p = 0.84, treatment 246 of 1,304 (18.9%), control 252 of 1,307 (19.3%), NNT 241, high-flow oxygen or ventilation. | |
| Gaitán-Duarte, 7/10/2021, Randomized Controlled Trial, Colombia, peer-reviewed, 17 authors, study period 24 August, 2020 - 20 March, 2021, average treatment delay 10.0 days, dosage 0.5mg days 1-14, this trial uses multiple treatments in the treatment arm (combined with rosuvastatin) - results of individual treatments may vary, trial NCT04359095 (history). | risk of death, 22.0% lower, HR 0.78, p = 0.38, treatment 22 of 153 (14.4%), control 28 of 161 (17.4%), NNT 33, adjusted per study, Cox proportional hazards. |
| Gertner, 5/15/2024, Randomized Controlled Trial, USA, peer-reviewed, mean age 58.0, 8 authors, study period 25 January, 2021 - 29 November, 2021, trial NCT04756128 (history) (COLTREXONE). | ICU/stepdown, 65.0% lower, OR 0.35, p = 0.11, treatment 67, control 70, adjusted per study, multivariable, RR approximated with OR. |
| recovery, 43.2% lower, OR 0.57, p = 0.14, treatment 67, control 70, adjusted per study, inverted to make OR<1 favor treatment, multivariable, day 5, RR approximated with OR. | |
| day of recovery, 24.2% lower, HR 0.76, p = 0.12, treatment 67, control 70, adjusted per study, inverted to make HR<1 favor treatment, multivariable, Cox proportional hazards, primary outcome. | |
| HFNC/NIPPV, 34.0% lower, OR 0.66, p = 0.34, treatment 67, control 70, adjusted per study, multivariable, RR approximated with OR. | |
| hospitalization time, 20.0% lower, relative time 0.80, p = 0.13, treatment 67, control 70, adjusted per study, multivariable. | |
| Gorial, 4/12/2022, Randomized Controlled Trial, Iraq, peer-reviewed, 6 authors, dosage 1mg days 1-7, 0.5mg days 8-15. | risk of death, 66.7% lower, RR 0.33, p = 0.62, treatment 1 of 80 (1.2%), control 3 of 80 (3.8%), NNT 40. |
| risk of no recovery, 62.8% lower, HR 0.37, p < 0.001, treatment 80, control 80, inverted to make HR<1 favor treatment, Cox proportional hazards. | |
| Haroon, 12/31/2022, Randomized Controlled Trial, Pakistan, peer-reviewed, median age 55.0, 23 authors, study period 8 December, 2020 - 7 July, 2021, trial NCT04667780 (history). | risk of no recovery, 33.8% lower, HR 0.66, p = 0.11, treatment 48, control 48, inverted to make HR<1 favor treatment. |
| Horby, 5/18/2021, Randomized Controlled Trial, United Kingdom, peer-reviewed, 35 authors, study period 27 November, 2020 - 4 March, 2021, average treatment delay 9.0 days, dosage 1.5mg day 1, 1mg days 2-10, dose for days 2-10 halved for certain patients, trial NCT04381936 (history) (RECOVERY), excluded in exclusion analyses: very late stage, 9 days since symptoms started, 32% baseline ventilation. | risk of death, 1.0% higher, RR 1.01, p = 0.85, treatment 1,394 of 5,610 (24.8%), control 1,408 of 5,730 (24.6%), day 180. |
| risk of death, 1.0% higher, RR 1.01, p = 0.77, treatment 1,173 of 5,610 (20.9%), control 1,190 of 5,730 (20.8%), day 28. | |
| risk of mechanical ventilation, 18.0% higher, RR 1.18, p = 0.06, treatment 259 of 3,815 (6.8%), control 228 of 3,962 (5.8%). | |
| risk of death/intubation, 2.0% higher, RR 1.02, p = 0.47, treatment 1,344 of 5,342 (25.2%), control 1,343 of 5,469 (24.6%). | |
| risk of no hospital discharge, 2.0% higher, RR 1.02, p = 0.44, treatment 1,709 of 5,610 (30.5%), control 1,698 of 5,730 (29.6%), inverted to make RR<1 favor treatment. | |
| Hueda-Zavaleta, 12/13/2022, retrospective, Peru, peer-reviewed, 9 authors, study period April 2020 - April 2021. | risk of death, 33.0% higher, HR 1.33, p = 0.33, treatment 18 of 52 (34.6%), control 33 of 148 (22.3%), Cox proportional hazards, Cox result from Chen et al. |
| Hueda-Zavaleta (B), 6/10/2021, retrospective, Peru, peer-reviewed, 6 authors, dosage not specified. | risk of death, 54.0% lower, HR 0.46, p = 0.03, treatment 10 of 50 (20.0%), control 109 of 301 (36.2%), NNT 6.2, adjusted per study, multivariable. |
| Jalal, 5/5/2022, Randomized Controlled Trial, Iraq, peer-reviewed, 3 authors, study period 8 May, 2021 - 18 June, 2021, trial NCT04867226 (history), excluded in exclusion analyses: minimal details provided. | hospitalization time, 24.1% lower, relative time 0.76, p = 0.009, treatment 36, control 44. |
| Karakaş, 1/31/2022, retrospective, Turkey, peer-reviewed, 11 authors, dosage 1mg daily, 0.5mg for 37 patients, excluded in exclusion analyses: excessive unadjusted differences between groups. | risk of death, 12.7% lower, RR 0.87, p = 0.72, treatment 16 of 165 (9.7%), control 19 of 171 (11.1%), NNT 71. |
| risk of ICU admission, 16.0% lower, RR 0.84, p = 0.50, treatment 30 of 165 (18.2%), control 37 of 171 (21.6%), NNT 29. | |
| hospitalization time, 25.0% lower, relative time 0.75, p < 0.001, treatment 165, control 171. | |
| Kasiri, 1/16/2023, Double Blind Randomized Controlled Trial, placebo-controlled, Iran, peer-reviewed, mean age 54.6, 6 authors, study period February 2021 - May 2021, average treatment delay 10.0 days, trial IRCT20190804044429N5. | risk of death, 7.3% lower, RR 0.93, p = 1.00, treatment 6 of 55 (10.9%), control 6 of 51 (11.8%), NNT 117. |
| risk of mechanical ventilation, 7.3% lower, RR 0.93, p = 1.00, treatment 6 of 55 (10.9%), control 6 of 51 (11.8%), NNT 117. | |
| risk of ICU admission, 23.6% higher, RR 1.24, p = 0.63, treatment 12 of 55 (21.8%), control 9 of 51 (17.6%). | |
| risk of no recovery, 27.9% lower, RR 0.72, p = 0.59, treatment 7 of 55 (12.7%), control 9 of 51 (17.6%), NNT 20, day 14. | |
| risk of no recovery, 11.7% lower, RR 0.88, p = 0.69, treatment 20 of 55 (36.4%), control 21 of 51 (41.2%), NNT 21, day 7. | |
| recovery time, 14.3% lower, relative time 0.86, p = 0.06, treatment 55, control 51. | |
| Landi, 5/28/2024, Randomized Controlled Trial, multiple countries, peer-reviewed, 11 authors, trial NCT04516941 (history) (CONVINCE). | risk of hospitalization, 4.0% higher, RR 1.04, p = 0.98, treatment 30, control 29. |
| risk of oxygen therapy, 5.0% higher, RR 1.05, p = 0.97, treatment 30, control 29. | |
| risk of analgesic need, 40.0% lower, RR 0.60, p = 0.97, treatment 30, control 29. | |
| risk of no viral clearance, 11.0% lower, RR 0.89, p = 0.77, treatment 30, control 29. | |
| Lopes, 8/12/2020, Double Blind Randomized Controlled Trial, Brazil, peer-reviewed, baseline oxygen required 93.0%, median age 54.5 (treatment) 55.0 (control), 34 authors, study period 11 April, 2020 - 30 August, 2020, average treatment delay 9.5 (treatment) 8.0 (control) days, dosage 1.5mg days 1-5, 1mg days 6-10. | risk of death, 80.0% lower, RR 0.20, p = 0.49, treatment 0 of 36 (0.0%), control 2 of 36 (5.6%), NNT 18, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| risk of ICU admission, 50.0% lower, RR 0.50, p = 0.67, treatment 2 of 36 (5.6%), control 4 of 36 (11.1%), NNT 18. | |
| hospitalization time, 22.2% lower, relative time 0.78, p < 0.01, treatment 36, control 36. | |
| Mahale, 12/31/2020, retrospective, India, peer-reviewed, 22 authors, study period 22 March, 2020 - 21 May, 2020, dosage not specified, excluded in exclusion analyses: unadjusted results with no group details. | risk of death, 7.2% higher, RR 1.07, p = 0.83, treatment 11 of 39 (28.2%), control 25 of 95 (26.3%). |
| Manenti, 3/24/2021, retrospective, Italy, peer-reviewed, 24 authors, study period 1 March, 2020 - 10 April, 2020, dosage 1mg days 1-21. | risk of death, 76.0% lower, HR 0.24, p = 0.005, treatment 71, control 70, adjusted per study, propensity score weighting. |
| risk of no recovery, 44.4% lower, RR 0.56, p = 0.048, treatment 71, control 70, adjusted per study, inverted to make RR<1 favor treatment, propensity score weighting. | |
| Mareev, 2/28/2021, retrospective, Russia, peer-reviewed, 21 authors, dosage 1mg days 1-3. | risk of death, 79.6% lower, RR 0.20, p = 0.49, treatment 0 of 21 (0.0%), control 2 of 22 (9.1%), NNT 11, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| ΔSHOCS-COVID, 50.0% lower, RR 0.50, p = 0.06, treatment 21, control 22, ΔSHOCS-COVID score, primary outcome. | |
| SHOCS-COVID, 71.4% lower, RR 0.29, p = 0.002, treatment 21, control 22, SHOCS-COVID score. | |
| NEWS-2, 66.7% lower, RR 0.33, p = 0.06, treatment 21, control 22, inverted to make RR<1 favor treatment, NEWS-2 score. | |
| hospitalization time, 25.7% lower, relative time 0.74, p = 0.08, treatment 21, control 22. | |
| Mehrizi, 12/18/2023, retrospective, Iran, peer-reviewed, 10 authors, study period 1 February, 2020 - 20 March, 2022. | risk of death, 13.0% higher, OR 1.13, p < 0.001, RR approximated with OR. |
| Pascual-Figal, 9/11/2021, Randomized Controlled Trial, Spain, peer-reviewed, 14 authors, study period 30 April, 2020 - 4 December, 2020, dosage 1.5mg day 1, 1mg days 2-8, 0.5mg days 9-36, trial NCT04350320 (history). | risk of death, 80.2% lower, RR 0.20, p = 0.24, treatment 0 of 52 (0.0%), control 2 of 51 (3.9%), NNT 26, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| risk of mechanical ventilation, 80.2% lower, RR 0.20, p = 0.24, treatment 0 of 52 (0.0%), control 2 of 51 (3.9%), NNT 26, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). | |
| risk of ICU admission, 51.0% lower, RR 0.49, p = 0.44, treatment 2 of 52 (3.8%), control 4 of 51 (7.8%), NNT 25. | |
| risk of 7-point scale, 87.5% lower, RR 0.13, p = 0.03, treatment 3 of 52 (5.8%), control 7 of 51 (13.7%), adjusted per study, odds ratio converted to relative risk, deterioration ≥1 point, multivariable, primary outcome. | |
| risk of 7-point scale, 80.2% lower, RR 0.20, p = 0.24, treatment 0 of 52 (0.0%), control 2 of 51 (3.9%), NNT 26, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm), deterioration ≥2 points. | |
| hospitalization time, 14.6% higher, relative time 1.15, p = 0.34, treatment 52, control 51. | |
| Perricone, 10/31/2022, Randomized Controlled Trial, Italy, peer-reviewed, mean age 69.1, 40 authors, study period 18 April, 2020 - 12 May, 2021, dosage 1.5mg daily, 2mg daily for >100kg, trial NCT04375202 (history) (COLVID-19). | risk of death, 36.4% higher, RR 1.36, p = 0.77, treatment 7 of 77 (9.1%), control 5 of 75 (6.7%). |
| risk of progression, 7.1% higher, RR 1.07, p = 1.00, treatment 11 of 77 (14.3%), control 10 of 75 (13.3%), mechanical ventilation, ICU, or death, primary outcome. | |
| risk of mechanical ventilation, 29.9% higher, RR 1.30, p = 1.00, treatment 4 of 77 (5.2%), control 3 of 75 (4.0%). | |
| risk of ICU admission, 75.6% lower, RR 0.24, p = 0.21, treatment 1 of 77 (1.3%), control 4 of 75 (5.3%), NNT 25. | |
| hospitalization time, 4.1% lower, relative time 0.96, p = 0.69, treatment mean 14.1 (±10.4) n=77, control mean 14.7 (±8.1) n=75. | |
| Pimenta Bonifácio, 4/28/2022, Randomized Controlled Trial, Brazil, peer-reviewed, mean age 48.9, 18 authors, study period 6 January, 2021 - 9 July, 2021, dosage 1.5mg days 1-3, 1mg days 4-28, trial NCT04724629 (history) (STRUCK). | risk of death, 78.9% lower, RR 0.21, p = 0.49, treatment 0 of 14 (0.0%), control 2 of 16 (12.5%), NNT 8.0, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| risk of no improvement, 84.9% lower, RR 0.15, p = 0.23, treatment 0 of 14 (0.0%), control 3 of 16 (18.8%), NNT 5.3, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). | |
| Pinzón, 10/23/2020, retrospective, Colombia, preprint, 9 authors, dosage 1mg days 1-14. | risk of death, 34.5% lower, RR 0.65, p = 0.18, treatment 14 of 145 (9.7%), control 23 of 156 (14.7%), NNT 20, odds ratio converted to relative risk. |
| Pourdowlat, 2/2/2022, Randomized Controlled Trial, Iran, peer-reviewed, 18 authors, study period 26 March, 2020 - 30 September, 2020. | risk of hospitalization, 72.8% lower, RR 0.27, p = 0.004, treatment 5 of 102 (4.9%), control 18 of 100 (18.0%), NNT 7.6. |
| relative improvement in dyspnea, 37.5% better, RR 0.62, p = 0.03, treatment 89, control 63, excluding 5 treatment and 37 control patients that needed hospitalization/other interventions. | |
| relative improvement in Ct score, 22.4% better, RR 0.78, p = 0.048, treatment 89, control 63, excluding 5 treatment and 37 control patients that needed hospitalization/other interventions. | |
| Rahman, 11/16/2022, Double Blind Randomized Controlled Trial, placebo-controlled, Bangladesh, peer-reviewed, 14 authors, study period June 2020 - November 2020, dosage 1.2mg day 1, 0.6mg days 2-14, trial NCT04527562 (history). | risk of death, 71.0% lower, HR 0.29, p = 0.04, treatment 4 of 146 (2.7%), control 13 of 146 (8.9%), NNT 16, Cox proportional hazards, day 28. |
| risk of progression, 71.0% lower, HR 0.29, p = 0.04, treatment 4 of 146 (2.7%), control 13 of 146 (8.9%), NNT 16, 2 point deterioration, Cox proportional hazards, day 28. | |
| risk of death, 61.0% lower, HR 0.39, p = 0.26, treatment 2 of 146 (1.4%), control 5 of 146 (3.4%), NNT 49, Cox proportional hazards, day 14. | |
| risk of mechanical ventilation, 51.0% lower, HR 0.49, p = 0.41, treatment 2 of 146 (1.4%), control 4 of 146 (2.7%), NNT 73, Cox proportional hazards, day 14. | |
| risk of progression, 56.0% lower, HR 0.44, p = 0.17, treatment 4 of 146 (2.7%), control 9 of 146 (6.2%), NNT 29, 2 point deterioration, Cox proportional hazards, day 14, primary outcome. | |
| Rodriguez-Nava, 11/5/2020, retrospective, USA, peer-reviewed, median age 68.0, 8 authors, dosage not specified, excluded in exclusion analyses: substantial unadjusted confounding by indication likely; excessive unadjusted differences between groups; unadjusted results with no group details. | risk of death, 5.5% lower, RR 0.94, p = 0.87, treatment 16 of 52 (30.8%), control 85 of 261 (32.6%), NNT 56, unadjusted. |
| Salehzadeh, 9/21/2020, Randomized Controlled Trial, Iran, peer-reviewed, median age 56.0, 3 authors, study period 21 May, 2020 - 20 June, 2020, average treatment delay 6.28 (treatment) 8.12 (control) days, trial IRCT20200418047126N1. | hospitalization time, 22.7% lower, relative time 0.77, p = 0.001, treatment 50, control 50. |
| Sandhu, 10/27/2020, prospective, USA, peer-reviewed, 4 authors, dosage 1.2mg days 1-3, 0.6mg days 4-15. | risk of death, 41.7% lower, RR 0.58, p < 0.001, treatment 16 of 34 (47.1%), control 63 of 78 (80.8%), NNT 3.0. |
| risk of mechanical ventilation, 52.9% lower, RR 0.47, p < 0.001, treatment 16 of 34 (47.1%), control 68 of 68 (100.0%), NNT 1.9. | |
| risk of no hospital discharge, 41.7% lower, RR 0.58, p < 0.001, treatment 16 of 34 (47.1%), control 63 of 78 (80.8%), NNT 3.0. | |
| Scarsi, 9/14/2020, retrospective, Italy, peer-reviewed, 28 authors, dosage 1mg daily, excluded in exclusion analyses: significant confounding by time possible due to separation of groups in different time periods. | risk of death, 84.9% lower, HR 0.15, p < 0.001, treatment 122, control 140. |
| Shah, 2/24/2023, Randomized Controlled Trial, USA, peer-reviewed, median age 61.0, 23 authors, study period October 2020 - September 2021, this trial uses multiple treatments in the treatment arm (combined with rosuvastatin) - results of individual treatments may vary, trial NCT04472611 (history) (COLSTAT), excluded in exclusion analyses: very late stage, >50% on oxygen/ventilation at baseline. | risk of death, 75.0% higher, RR 1.75, p = 0.54, treatment 7 of 125 (5.6%), control 4 of 125 (3.2%), day 60. |
| risk of death, 100% higher, RR 2.00, p = 0.50, treatment 6 of 125 (4.8%), control 3 of 125 (2.4%), day 30. | |
| risk of mechanical ventilation, 200.0% higher, RR 3.00, p = 0.28, treatment 6 of 125 (4.8%), control 2 of 125 (1.6%). | |
| risk of severe case, 46.2% higher, RR 1.46, p = 0.34, treatment 19 of 125 (15.2%), control 13 of 125 (10.4%), day 60, primary outcome. | |
| risk of severe case, 72.7% higher, RR 1.73, p = 0.17, treatment 19 of 125 (15.2%), control 11 of 125 (8.8%), day 30, primary outcome. | |
| Sunil Naik, 1/21/2023, Randomized Controlled Trial, India, peer-reviewed, 3 authors, trial CTRI/2021/03/032060. | risk of death, 169.4% higher, RR 2.69, p = 1.00, treatment 1 of 62 (1.6%), control 0 of 43 (0.0%), continuity correction due to zero event (with reciprocal of the contrasting arm). |
| risk of progression, 108.1% higher, RR 2.08, p = 0.64, treatment 3 of 62 (4.8%), control 1 of 43 (2.3%). | |
| recovery, 7.3% lower, RR 0.93, p = 0.21, treatment 62, control 43, relative improvement in ordinal score. | |
| risk of no recovery, 15.0% lower, RR 0.85, p = 0.06, treatment 49 of 62 (79.0%), control 40 of 43 (93.0%), NNT 7.1, ordinal score ≤1. | |
| recovery, 24.3% lower, RR 0.76, p = 0.02, treatment 62, control 43, relative improvement in CT score. | |
| Tardif, 1/27/2021, Double Blind Randomized Controlled Trial, multiple countries, peer-reviewed, 44 authors, study period 23 March, 2020 - 21 January, 2021, average treatment delay 5.3 days, dosage 1mg days 1-3, 0.5mg days 4-30, trial NCT04322682 (history) (COLCORONA). | risk of death, 43.9% lower, RR 0.56, p = 0.30, treatment 5 of 2,235 (0.2%), control 9 of 2,253 (0.4%), NNT 569, odds ratio converted to relative risk. |
| risk of death/hospitalization, 20.0% lower, RR 0.80, p = 0.08, treatment 104 of 2,235 (4.7%), control 131 of 2,253 (5.8%), NNT 86, odds ratio converted to relative risk, primary outcome. | |
| risk of mechanical ventilation, 46.8% lower, RR 0.53, p = 0.09, treatment 11 of 2,235 (0.5%), control 21 of 2,253 (0.9%), NNT 227, odds ratio converted to relative risk. | |
| risk of hospitalization, 20.0% lower, RR 0.80, p = 0.09, treatment 101 of 2,235 (4.5%), control 128 of 2,253 (5.7%), NNT 86, odds ratio converted to relative risk. | |
| Valerio Pascua, 1/7/2021, retrospective, multiple countries, peer-reviewed, 19 authors, study period 10 June, 2020 - 6 August, 2020, average treatment delay 6.1 days, dosage 1.5mg day 1, 1mg days 2-5, varied by location, this trial uses multiple treatments in the treatment arm (combined with LMWH, tocilizumab, dexamethasone, methylprednisolone) - results of individual treatments may vary. | risk of death, 22.8% lower, RR 0.77, p = 0.60, treatment 5 of 35 (14.3%), control 12 of 30 (40.0%), NNT 3.9, adjusted per study, odds ratio converted to relative risk, multivariable. |
| ICU time, 39.9% lower, relative time 0.60, p = 0.03, treatment 35, control 30, adjusted per study, multivariable. | |
| Vaziri, 3/6/2024, Randomized Controlled Trial, Iran, peer-reviewed, mean age 54.2, 11 authors, study period April 2020 - December 2020, this trial uses multiple treatments in the treatment arm (combined with phenolic monoterpenes) - results of individual treatments may vary, trial NCT04392141 (history), excluded in exclusion analyses: randomization resulted in significant baseline differences that were not adjusted for. | risk of death, 81.2% lower, RR 0.19, p = 0.03, treatment 2 of 108 (1.9%), control 7 of 71 (9.9%), NNT 12, after 14 day followup. |
| risk of death, 89.0% lower, RR 0.11, p = 0.02, treatment 1 of 108 (0.9%), control 6 of 71 (8.5%), NNT 13, in hospital. | |
| risk of ICU admission, 86.9% lower, RR 0.13, p = 0.002, treatment 2 of 108 (1.9%), control 10 of 71 (14.1%), NNT 8.2. | |
| hospitalization time, 34.7% lower, relative time 0.65, p < 0.001, treatment mean 4.17 (±1.34) n=108, control mean 6.39 (±2.59) n=71. | |
| Villamañán, 3/23/2023, retrospective, Spain, peer-reviewed, median age 79.0, 10 authors, study period March 2020 - June 2020. | risk of death, 41.9% lower, RR 0.58, p = 0.03, treatment 19 of 111 (17.1%), control 32 of 111 (28.8%), NNT 8.5, odds ratio converted to relative risk. |
| Yadollahzadeh, 2/29/2024, Randomized Controlled Trial, Iran, peer-reviewed, 10 authors, trial IRCT20200325046854N2. | risk of death, 33.3% lower, RR 0.67, p = 0.54, treatment 6 of 26 (23.1%), control 9 of 26 (34.6%), NNT 8.7. |
Effect extraction follows pre-specified rules as detailed above
and gives priority to more serious outcomes.
For pooled analyses, the first (most serious) outcome is used, which may
differ from the effect a paper focuses on.
Other outcomes are used in outcome specific analyses.
| Avanoglu Guler, 7/21/2022, retrospective, Turkey, peer-reviewed, median age 39.5, 14 authors. | risk of oxygen therapy, 78.8% lower, RR 0.21, p = 0.04, treatment 6 of 66 (9.1%), control 3 of 7 (42.9%), NNT 3.0, inverted to make RR<1 favor treatment, odds ratio converted to relative risk. |
| Chevalier, 3/22/2023, retrospective, France, peer-reviewed, mean age 70.3, 24 authors. | risk of death, 27.8% higher, RR 1.28, p = 0.54, treatment 5 of 21 (23.8%), control 111 of 569 (19.5%), odds ratio converted to relative risk. |
| risk of hospitalization, 7.6% lower, RR 0.92, p = 0.83, treatment 15 of 116 (12.9%), control 180 of 1,097 (16.4%), odds ratio converted to relative risk. | |
| Correa-Rodríguez, 9/19/2022, retrospective, Spain, peer-reviewed, mean age 44.0, 6 authors. | risk of oxygen therapy, 149.7% higher, RR 2.50, p = 1.00, treatment 1 of 163 (0.6%), control 0 of 81 (0.0%), continuity correction due to zero event (with reciprocal of the contrasting arm). |
| risk of hospitalization, 149.7% higher, RR 2.50, p = 1.00, treatment 1 of 163 (0.6%), control 0 of 81 (0.0%), continuity correction due to zero event (with reciprocal of the contrasting arm). | |
| risk of no recovery, 7.1% lower, RR 0.93, p = 1.00, treatment 13 of 24 (54.2%), control 7 of 12 (58.3%), NNT 24, full recovery at 6 months. | |
| risk of case, 0.6% lower, RR 0.99, p = 1.00, treatment 24 of 163 (14.7%), control 12 of 81 (14.8%), NNT 1100. | |
| Madrid-García, 1/31/2021, retrospective, Spain, peer-reviewed, 8 authors, study period 1 March, 2020 - 20 May, 2020. | risk of death, 37.1% higher, HR 1.37, p = 0.57. |
| risk of hospitalization, 137.0% higher, HR 2.37, p = 0.20, GBM. | |
| Monserrat Villatoro, 1/8/2022, retrospective, propensity score matching, Spain, peer-reviewed, 18 authors. | risk of death, 80.0% lower, OR 0.20, p = 0.02, RR approximated with OR. |
| Ozcifci, 11/25/2021, prospective, Turkey, peer-reviewed, 13 authors, study period 1 April, 2020 - 30 April, 2021. | risk of case, 4.0% lower, RR 0.96, p = 0.72, treatment 130 of 616 (21.1%), control 85 of 421 (20.2%), odds ratio converted to relative risk. |
| Oztas, 3/21/2022, retrospective, Turkey, peer-reviewed, 15 authors, excluded in exclusion analyses: excessive unadjusted differences between groups. | risk of hospitalization, 406.3% higher, RR 5.06, p = 0.12, treatment 5 of 635 (0.8%), control 1 of 643 (0.2%). |
| risk of symptomatic case, 72.7% higher, RR 1.73, p = 0.07, treatment 29 of 635 (4.6%), control 17 of 643 (2.6%). | |
| risk of case, 24.4% higher, RR 1.24, p = 0.35, treatment 43 of 635 (6.8%), control 35 of 643 (5.4%). | |
| Sáenz-Aldea, 1/13/2023, retrospective, Spain, peer-reviewed, 8 authors. | risk of hospitalization, 8.0% higher, OR 1.08, p = 0.68, treatment 36 of 3,060 (1.2%) cases, 459 of 56,785 (0.8%) controls, case control OR. |
| risk of case, 12.0% higher, OR 1.12, p = 0.68, treatment 140 of 29,817 (0.5%) cases, 459 of 56,875 (0.8%) controls, NNT 9.0, case control OR. | |
| Topless, 1/28/2022, retrospective, database analysis, United Kingdom, peer-reviewed, 6 authors, dosage not specified. | risk of death, 23.2% lower, OR 0.77, p = 0.12, relative odds for patients with gout, model 2, RR approximated with OR. |
Viral infection and replication involves attachment, entry, uncoating and release, genome replication and transcription, translation and protein processing, assembly and budding, and release. Each step can be disrupted by therapeutics.
Monoclonal antibodies were
previously included. Other treatments such as dexamethasone, tocilizumab, and baricitinib
were recommended for late stage hospitalized patients.
Smoking was
known to cause lung cancer since at least 1939, but this was not widely recognized in the
US until 1964, 25 years later. Surgeon general Leroy Burney tried publicizing the danger
starting in 1957, with limited success. Surgeon general Luther Terry, appointed in 1961,
prompted by President Kennedy in 1962 amid pressure from health advocates, finally got
recognition in 1964. The 1964 report reviewed 7,000+ studies, but these could (and should)
have been reviewed and acted upon in real-time as they were published.
Historians attribute the 25 year delay to an industry campaign to manufacture doubt and
controversy, through tactics like funding biased and fraudulent research from
"independent" organizations, attacking scientists, and political lobbying.
The success of the industry campaign is only possible because officials did not analyze
the research in detail. Fraudulent industry research supported prior failures, but would
have been called out as fraudulent by officials that analyzed and understood the research
in real-time.
When administered late in infection, HCQ may enhance viral egress by further increasing
lysosomal pH beyond the effect of ORF3a's water channel activity, thereby promoting
lysosomal exocytosis, inactivating degradative enzymes, and facilitating the release of
SARS-CoV-2 particles into the extracellular environment260,261.
Research also suggests potential cardioprotective effects at lower doses, but
cardiotoxicity with excessive dosage262. Bobrowski et al. also
indicate negative effects if HCQ and remdesivir are combined.
Peters (B) et al. is subject to confounding by calendar-time (SOC evolved rapidly early in
the pandemic, the linear covariate does not reflect non-linear SOC changes and hospital
specific effects), hospital type (non-treatment hospitals were tertiary university
centers), confounding by indication (4/7 hospitals initiated treatment on deterioration),
immortal-time bias for as-treated (exposure assigned after baseline), significant
differences for other experimental treatments, potential overadjustment from collider bias
(steroid use and indication bias), limited baseline severity information, differences in
hospice referral propensity across hospitals, unadjusted difference in time from onset to
admission, difference in PCR positivity, and other factors.
Mahévas et al. is subject to confounding by hospital (treatment highly dependent on
the hospital, different SOC/ICU transfer practices, not included in PS), immortal time
(only partly addressed in sensitivity analysis), co-treatment differences, calendar-time
(SOC evolved rapidly early in the pandemic), binary coding for age (age ≥65 despite steep
age-risk gradient), residual imbalance (variables dropped from PS), a composite outcome
dependent on hospital triage/capacity, and other factors.
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