Aspirin for COVID-19: real-time meta-analysis of 79 studies

Abstract
Significantly lower risk is seen for mortality and progression. 28 studies from 26 independent teams in 11 countries show significant benefit.
Meta-analysis using the most serious outcome reported shows 8% [2‑13%] lower risk. Early treatment is more effective than late treatment.
Studies to date do not show a significant benefit for mechanical ventilation, ICU admission, or hospitalization. Bunditanukul et al. show increased risk of major bleeding. Benefit may be more likely without coadministered anticoagulants. The RECOVERY RCT shows 4% [-4‑11%] lower mortality for all patients, however when restricting to non-LMWH patients there was 17% [-4‑34%] improvement, comparable with the mortality results of all studies, 8% [2‑14%], and the 16% improvement in the REMAP-CAP RCT.
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.
4 other meta-analyses show significant improvements with aspirin for mortality2-4, mechanical ventilation2, and progression5.
Evolution of COVID-19 clinical evidence Meta-analysis results over time Aspirin p=0.015 Acetaminophen p=0.00000021 2020 2021 2022 2023 2024 2025 2026 Lowerrisk Higherrisk c19early.org October 2026 50% 0% -50%
Aspirin for COVID-19 — Highlights
Aspirin reduces risk with very high confidence for mortality and progression, high confidence for pooled analysis, and low confidence for recovery and viral clearance.
Benefit may be more likely without coadministered anticoagulants. May increase major bleeding risk.
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.
October 2026

Aspirin COVID-19 studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Alamdari−28%1.28 · 0.67–2.43death9/5354/406 Husain80%0.20 · 0.01–3.55death0/113/31 Goshua (PSM)35%0.65 · 0.42–0.98death319 (n)319 (n) Meizlish (PSM)48%0.52 · 0.34–0.81death319 (n)319 (n) Liu (PSM)75%0.25 · 0.07–0.87death2/2811/204 Mura (PSM)15%0.85 · 0.69–1.01death527 (n)527 (n) Chow47%0.53 · 0.31–0.90death26/9873/314 Haji Aghajani25%0.75 · 0.57–0.99death336 (n)655 (n) Elhadi (ICU)10%0.90 · 0.67–1.21death22/40259/425ICU patients Sahai (PSM)13%0.87 · 0.56–1.34death33/24838/248 Pourhoseingholi−32%1.32 · 1.02–1.71death71/290268/2,178 Vahedian-Azimi22%0.78 · 0.33–1.74death13/33728/250 Abdelwahab−8%1.08 · 0.15–3.82ventilation11/316/36 Karruli (ICU)46%0.54 · 0.09–3.13death1/522/27ICU patients Al Harthi (ICU)27%0.73 · 0.56–0.97death98/176107/173ICU patients Kim (PSM)34%0.66 · 0.36–1.23death14/12423/135 Zhao43%0.57 · 0.41–0.78death121/473140/473 Horby (RCT)4%0.96 · 0.89–1.04death7,351 (n)7,541 (n)RECOVERY Mustafa44%0.56 · 0.21–1.51death4/6641/378 Bradbury (RCT)16%0.84 · 0.70–1.00death165/563170/521REMAP-CAP Chow (PSW)13%0.87 · 0.81–0.93deathpopulation-based cohort Santoro (PSM)38%0.62 · 0.42–0.92death360 (n)2,949 (n) Ghati (RCT)22%0.78 · 0.31–1.98death11/4427/219RESIST Karimpour-Razke..−123%2.23 · 1.26–3.38death39/9064/363 Eikelboom (RCT)−5%1.05 · 0.86–1.28death193/1,063186/1,056ACT inpatientCT1 Eikelboom (RCT)−9%1.09 · 0.48–2.46death12/1,94511/1,936ACT outpatient Ali (ICU)40%0.60 · 0.51–0.72death152/660202/530ICU patients Aidouni (ICU)31%0.69 · 0.54–0.88death202/712165/412ICU patients Singla (RCT)57%0.43 · 0.04–3.27death3/495/49CT1 Shamsi96%0.04 · 0.00–0.58death0/1324/170 Mehrizi16%0.84 · 0.82–0.86deathpopulation-based cohort Lewandowski−70%1.70 · 1.08–2.70death430 (all patients) Vinod14%0.86 · 0.48–1.52death128 (n)248 (n) Azimi Pirsaraei−97%1.97 · 1.28–3.04death28/18450/647 Dinoi−55%1.55 · 1.05–2.30deathcase-control study
Late treatment14%0.86 · 0.80–0.931,230/17,0411,957/23,73914% lower risk
Tau² = 0.02, I² = 78.9%, p = 0.00036
Holt−34%1.34 · 0.98–1.84death/ICU35/116129/573 Wang58%0.42 · 0.01–1.98death1/913/49 Lodigiani−21%1.21 · 0.73–2.01ICU17/9444/294 Yuan4%0.96 · 0.47–1.72death11/5229/131 Ramos-Rincón−29%1.29 · 1.05–1.51death132/264253/526 Osborne (PSM)59%0.41 · 0.35–0.48death272/6,300661/6,300 Merzon28%0.72 · 0.53–0.99cases73/1,621589/8,856 Bejan1%0.99 · 0.61–1.63ventilation1,899 (n)7,330 (n) Mulhem−14%1.14 · 0.93–1.40death300/1,354216/1,865 Reese (PSM)−61%1.61 · 1.31–1.99death4,921 (n)4,921 (n) Drew22%0.78 · 0.49–1.24progressionn/an/a Pan−13%1.13 · 0.70–1.82death239 (n)523 (n) Oh1%0.99 · 0.65–1.50deathn/an/a Son (PSM)11%0.89 · 0.53–1.47deathcase-control study Ma (PSM)9%0.91 · 0.82–1.02death Chow (PSM)19%0.81 · 0.76–0.87death1,280/6,7812,271/10,566 Kim (PSM)−700%8.00 · 1.07–59.61death6/151/20 Basheer−13%1.13 · 1.05–1.21death45/14029/250 Sisinni−7%1.07 · 0.89–1.29death93/253251/731 Pérez-Segura−49%1.49 · 1.20–1.80death66/155183/608 Formiga (PSM)−3%1.03 · 0.94–1.13death1,000/3,291874/2,885 Sullerot (PSW)−10%1.10 · 0.81–1.49death101/301224/746 Monserrat .. (PSM)−31%1.31 · 1.01–1.71deathn/an/a Levy26%0.74 · 0.49–1.10death/hosp.29/159178/690 Nimer4%0.96 · 0.69–1.33hosp.83/427136/1,721 Gogtay−6%1.06 · 0.51–1.89death12/3821/87 Campbell (PSW)3%0.97 · 0.95–1.00death419 (n)20,311 (n) Lal11%0.89 · 0.82–0.97death4,691 (n)16,888 (n) Botton−4%1.04 · 0.98–1.10death/int.population-based cohort Malik14%0.86 · 0.39–1.80death15/8724/223 Abul33%0.67 · 0.47–0.95death46/511201/1,176 Loucera18%0.82 · 0.74–0.92death2,127 (n)13,841 (n) Morrison (PSM)8%0.92 · 0.73–1.18death1,667 (n)1,667 (n) Ali28%0.72 · 0.51–1.03death481 (n)1,164 (n) Zadeh37%0.63 · 0.30–1.29deathn/an/a Azizi0%1.00 · 0.53–1.87death17/13117/131 Aweimer−10%1.10 · 0.90–1.34death34/4474/105Intubated patients Tse (PSM)67%0.33 · 0.18–0.59death/int.2,664 (all patients) Prieto-Campo−13%1.13 · 0.86–1.48deathcase-control study Ware (PSM)46%0.54 · 0.53–0.56deathpopulation-based cohort Sakamaki−37%1.37 · 1.31–1.44severe casepopulation-based cohort Miele−32%1.32 · 1.04–1.68deathn/an/a Kurnik (ICU)−11%1.11 · 0.92–1.34death33/4067/90ICU patients
Prophylaxis4%0.96 · 0.88–1.063,701/38,6276,485/105K4% lower risk
Tau² = 0.07, I² = 95.0%, p = 0.44
All studies8%0.92 · 0.87–0.984,931/55,8128,443/129K8% lower risk
Tau² = 0.05, I² = 92.8%, p = 0.01500.511.52+
1 CT: study uses combined treatment
Rotate screen for more detailsIncrease width for more details
← Aspirin
reduces risk
Aspirin
increases risk →
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 aspirin studies.
Fig. 2. SARS-CoV-2 spike protein fibrin binding leads to thromboinflammation and neuropathology, from6.
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 injury7-23 and cognitive deficits10,15, cardiovascular complications24-30, DNA damage31-34, organ failure, and death. Even mild untreated infections may result in persistent cognitive deficits35—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,36-43, providing many therapeutic targets for which many existing compounds have known activity. Scientists have predicted that over 12,000 compounds may reduce COVID-19 risk44, either by directly minimizing infection or replication, by supporting immune system function, or by minimizing secondary complications.
We analyze all significant controlled studies of aspirin 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.
Prophylaxis pre-exposure post-exposure Early treatment Late treatment Treatment delay viral load disease severity exposed symptom onset hospitalized ICU Expected benefit of antiviral therapy −2 0 2 4 6 8 10 Time relative to symptom onset (days) trajectories vary widely immediately or soon after symptoms after disease progression
Fig. 3. Treatment stages.
An in silico study supports the efficacy of aspirin45.
3 in vitro studies support the efficacy of aspirin46-48.
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 1 summarizes the results for all stages combined, for Randomized Controlled Trials, for peer-reviewed studies, after exclusions, and for specific outcomes. Table 2 shows results 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.
Table 1. Random-effects meta-analysis for all stages combined, for Randomized Controlled Trials, for peer-reviewed studies, after exclusions, and for specific outcomes. Results show the relative risk with treatment and the 95% confidence interval. * p<0.05  *** p<0.001  **** p<0.0001.
Relative Risk Studies Patients
All studies0.92 [0.87‑0.98]*79180K
After exclusions0.88 [0.82‑0.94]***67180K
Peer-reviewedPeer-reviewed0.92 [0.86‑0.98]**70170K
RCTsRCTs0.95 [0.89‑1.02]720K
Mortality0.92 [0.86‑0.98]**68160K
VentilationVent.0.95 [0.85‑1.05]1550K
ICU admissionICU0.97 [0.84‑1.11]1530K
HospitalizationHosp.1.01 [0.96‑1.06]1010K
Recovery0.91 [0.82‑1.01]310K
Cases0.95 [0.86‑1.05]710K
Viral0.91 [0.83‑1.00]2710
RCT mortality0.95 [0.89‑1.02]620K
Table 2. Random-effects meta-analysis results by treatment stage. Results show the relative risk with treatment and the 95% confidence interval.treatment and the 95% confidence interval. * p<0.05  *** p<0.001  **** p<0.0001.
Early treatment Late treatment Prophylaxis
All studies0.33 [0.01‑7.96]0.33
[0.01‑7.96]
0.86 [0.80‑0.93]***0.86***
[0.80‑0.93]
0.96 [0.88‑1.06]0.96
[0.88‑1.06]
After exclusions0.33 [0.01‑7.96]0.33
[0.01‑7.96]
0.82 [0.76‑0.88]****0.82****
[0.76‑0.88]
0.93 [0.84‑1.03]0.93
[0.84‑1.03]
Peer-reviewedPeer-reviewed0.33 [0.01‑7.96]0.33
[0.01‑7.96]
0.86 [0.79‑0.93]***0.86***
[0.79‑0.93]
0.96 [0.88‑1.05]0.96
[0.88‑1.05]
RCTsRCTs0.33 [0.01‑7.96]0.33
[0.01‑7.96]
0.95 [0.89‑1.02]0.95
[0.89‑1.02]
Mortality0.86 [0.79‑0.93]***0.86***
[0.79‑0.93]
0.97 [0.87‑1.08]0.97
[0.87‑1.08]
VentilationVent.0.92 [0.75‑1.14]0.92
[0.75‑1.14]
0.98 [0.93‑1.02]0.98
[0.93‑1.02]
ICU admissionICU0.97 [0.70‑1.35]0.97
[0.70‑1.35]
0.98 [0.83‑1.16]0.98
[0.83‑1.16]
HospitalizationHosp.0.33 [0.01‑7.96]0.33
[0.01‑7.96]
0.83 [0.58‑1.19]0.83
[0.58‑1.19]
1.01 [0.96‑1.07]1.01
[0.96‑1.07]
Recovery0.91 [0.82‑1.01]0.91
[0.82‑1.01]
Cases0.95 [0.86‑1.05]0.95
[0.86‑1.05]
Viral1.02 [0.64‑1.61]1.02
[0.64‑1.61]
0.90 [0.82‑1.00]*0.90*
[0.82‑1.00]
RCT mortality0.95 [0.89‑1.02]0.95
[0.89‑1.02]
Loading..
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.
October 2026

Aspirin COVID-19 studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Alamdari−28%1.28 · 0.67–2.43death9/5354/406 Husain80%0.20 · 0.01–3.55death0/113/31 Goshua (PSM)35%0.65 · 0.42–0.98death319 (n)319 (n) Meizlish (PSM)48%0.52 · 0.34–0.81death319 (n)319 (n) Liu (PSM)75%0.25 · 0.07–0.87death2/2811/204 Mura (PSM)15%0.85 · 0.69–1.01death527 (n)527 (n) Chow47%0.53 · 0.31–0.90death26/9873/314 Haji Aghajani25%0.75 · 0.57–0.99death336 (n)655 (n) Elhadi (ICU)10%0.90 · 0.67–1.21death22/40259/425ICU patients Sahai (PSM)13%0.87 · 0.56–1.34death33/24838/248 Pourhoseingholi−32%1.32 · 1.02–1.71death71/290268/2,178 Vahedian-Azimi22%0.78 · 0.33–1.74death13/33728/250 Abdelwahab−8%1.08 · 0.15–3.82ventilation11/316/36 Karruli (ICU)46%0.54 · 0.09–3.13death1/522/27ICU patients Al Harthi (ICU)27%0.73 · 0.56–0.97death98/176107/173ICU patients Kim (PSM)34%0.66 · 0.36–1.23death14/12423/135 Zhao43%0.57 · 0.41–0.78death121/473140/473 Horby (RCT)4%0.96 · 0.89–1.04death7,351 (n)7,541 (n)RECOVERY Mustafa44%0.56 · 0.21–1.51death4/6641/378 Bradbury (RCT)16%0.84 · 0.70–1.00death165/563170/521REMAP-CAP Chow (PSW)13%0.87 · 0.81–0.93deathpopulation-based cohort Santoro (PSM)38%0.62 · 0.42–0.92death360 (n)2,949 (n) Ghati (RCT)22%0.78 · 0.31–1.98death11/4427/219RESIST Karimpour-Razke..−123%2.23 · 1.26–3.38death39/9064/363 Eikelboom (RCT)−5%1.05 · 0.86–1.28death193/1,063186/1,056ACT inpatientCT1 Eikelboom (RCT)−9%1.09 · 0.48–2.46death12/1,94511/1,936ACT outpatient Ali (ICU)40%0.60 · 0.51–0.72death152/660202/530ICU patients Aidouni (ICU)31%0.69 · 0.54–0.88death202/712165/412ICU patients Singla (RCT)57%0.43 · 0.04–3.27death3/495/49CT1 Shamsi96%0.04 · 0.00–0.58death0/1324/170 Mehrizi16%0.84 · 0.82–0.86deathpopulation-based cohort Lewandowski−70%1.70 · 1.08–2.70death430 (all patients) Vinod14%0.86 · 0.48–1.52death128 (n)248 (n) Azimi Pirsaraei−97%1.97 · 1.28–3.04death28/18450/647 Dinoi−55%1.55 · 1.05–2.30deathcase-control study
Late treatment14%0.86 · 0.80–0.931,230/17,0411,957/23,73914% lower risk
Tau² = 0.02, I² = 78.9%, p = 0.00036
Holt−34%1.34 · 0.98–1.84death/ICU35/116129/573 Wang58%0.42 · 0.01–1.98death1/913/49 Lodigiani−21%1.21 · 0.73–2.01ICU17/9444/294 Yuan4%0.96 · 0.47–1.72death11/5229/131 Ramos-Rincón−29%1.29 · 1.05–1.51death132/264253/526 Osborne (PSM)59%0.41 · 0.35–0.48death272/6,300661/6,300 Merzon28%0.72 · 0.53–0.99cases73/1,621589/8,856 Bejan1%0.99 · 0.61–1.63ventilation1,899 (n)7,330 (n) Mulhem−14%1.14 · 0.93–1.40death300/1,354216/1,865 Reese (PSM)−61%1.61 · 1.31–1.99death4,921 (n)4,921 (n) Drew22%0.78 · 0.49–1.24progressionn/an/a Pan−13%1.13 · 0.70–1.82death239 (n)523 (n) Oh1%0.99 · 0.65–1.50deathn/an/a Son (PSM)11%0.89 · 0.53–1.47deathcase-control study Ma (PSM)9%0.91 · 0.82–1.02death Chow (PSM)19%0.81 · 0.76–0.87death1,280/6,7812,271/10,566 Kim (PSM)−700%8.00 · 1.07–59.61death6/151/20 Basheer−13%1.13 · 1.05–1.21death45/14029/250 Sisinni−7%1.07 · 0.89–1.29death93/253251/731 Pérez-Segura−49%1.49 · 1.20–1.80death66/155183/608 Formiga (PSM)−3%1.03 · 0.94–1.13death1,000/3,291874/2,885 Sullerot (PSW)−10%1.10 · 0.81–1.49death101/301224/746 Monserrat .. (PSM)−31%1.31 · 1.01–1.71deathn/an/a Levy26%0.74 · 0.49–1.10death/hosp.29/159178/690 Nimer4%0.96 · 0.69–1.33hosp.83/427136/1,721 Gogtay−6%1.06 · 0.51–1.89death12/3821/87 Campbell (PSW)3%0.97 · 0.95–1.00death419 (n)20,311 (n) Lal11%0.89 · 0.82–0.97death4,691 (n)16,888 (n) Botton−4%1.04 · 0.98–1.10death/int.population-based cohort Malik14%0.86 · 0.39–1.80death15/8724/223 Abul33%0.67 · 0.47–0.95death46/511201/1,176 Loucera18%0.82 · 0.74–0.92death2,127 (n)13,841 (n) Morrison (PSM)8%0.92 · 0.73–1.18death1,667 (n)1,667 (n) Ali28%0.72 · 0.51–1.03death481 (n)1,164 (n) Zadeh37%0.63 · 0.30–1.29deathn/an/a Azizi0%1.00 · 0.53–1.87death17/13117/131 Aweimer−10%1.10 · 0.90–1.34death34/4474/105Intubated patients Tse (PSM)67%0.33 · 0.18–0.59death/int.2,664 (all patients) Prieto-Campo−13%1.13 · 0.86–1.48deathcase-control study Ware (PSM)46%0.54 · 0.53–0.56deathpopulation-based cohort Sakamaki−37%1.37 · 1.31–1.44severe casepopulation-based cohort Miele−32%1.32 · 1.04–1.68deathn/an/a Kurnik (ICU)−11%1.11 · 0.92–1.34death33/4067/90ICU patients
Prophylaxis4%0.96 · 0.88–1.063,701/38,6276,485/105K4% lower risk
Tau² = 0.07, I² = 95.0%, p = 0.44
All studies8%0.92 · 0.87–0.984,931/55,8128,443/129K8% lower risk
Tau² = 0.05, I² = 92.8%, p = 0.01500.511.52+
1 CT: study uses combined treatment
Rotate screen for more detailsIncrease width for more details
← Aspirin
reduces risk
Aspirin
increases risk →
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.
October 2026

Aspirin COVID-19 mortality results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Alamdari−28%1.28 · 0.67–2.439/5354/406 Husain80%0.20 · 0.01–3.550/113/31 Goshua (PSM)35%0.65 · 0.42–0.98319 (n)319 (n) Meizlish (PSM)48%0.52 · 0.34–0.81319 (n)319 (n) Liu (PSM)75%0.25 · 0.07–0.872/2811/204 Mura (PSM)15%0.85 · 0.69–1.01527 (n)527 (n) Chow47%0.53 · 0.31–0.9026/9873/314 Haji Aghajani25%0.75 · 0.57–0.99336 (n)655 (n) Elhadi (ICU)10%0.90 · 0.67–1.2122/40259/425ICU patients Sahai (PSM)13%0.87 · 0.56–1.3433/24838/248 Pourhoseingholi−32%1.32 · 1.02–1.7171/290268/2,178 Vahedian-Azimi22%0.78 · 0.33–1.7413/33728/250 Karruli (ICU)46%0.54 · 0.09–3.131/522/27ICU patients Al Harthi (ICU)27%0.73 · 0.56–0.9798/176107/173ICU patients Kim (PSM)34%0.66 · 0.36–1.2314/12423/135 Zhao43%0.57 · 0.41–0.78121/473140/473 Horby (RCT)4%0.96 · 0.89–1.047,351 (n)7,541 (n)RECOVERY Mustafa44%0.56 · 0.21–1.514/6641/378 Bradbury (RCT)16%0.84 · 0.70–1.00165/563170/521REMAP-CAP Chow (PSW)13%0.87 · 0.81–0.93population-based cohort Santoro (PSM)38%0.62 · 0.42–0.92360 (n)2,949 (n) Ghati (RCT)22%0.78 · 0.31–1.9811/4427/219RESIST Karimpour-Razke..−123%2.23 · 1.26–3.3839/9064/363 Eikelboom (RCT)−5%1.05 · 0.86–1.28193/1,063186/1,056ACT inpatientCT1 Eikelboom (RCT)−9%1.09 · 0.48–2.4612/1,94511/1,936ACT outpatient Ali (ICU)40%0.60 · 0.51–0.72152/660202/530ICU patients Aidouni (ICU)31%0.69 · 0.54–0.88202/712165/412ICU patients Singla (RCT)57%0.43 · 0.04–3.273/495/49CT1 Shamsi96%0.04 · 0.00–0.580/1324/170 Mehrizi16%0.84 · 0.82–0.86population-based cohort Lewandowski−70%1.70 · 1.08–2.70430 (all patients) Vinod14%0.86 · 0.48–1.52128 (n)248 (n) Azimi Pirsaraei−97%1.97 · 1.28–3.0428/18450/647 Dinoi−55%1.55 · 1.05–2.30case-control study
Late treatment14%0.86 · 0.79–0.931,219/17,0101,951/23,70314% lower risk
Tau² = 0.02, I² = 79.5%, p = 0.00033
Wang58%0.42 · 0.01–1.981/913/49 Yuan4%0.96 · 0.47–1.7211/5229/131 Ramos-Rincón−29%1.29 · 1.05–1.51132/264253/526 Osborne (PSM)59%0.41 · 0.35–0.48272/6,300661/6,300 Merzon62%0.38 · 0.02–4.941/216/91 Mulhem−14%1.14 · 0.93–1.40300/1,354216/1,865 Reese (PSM)−61%1.61 · 1.31–1.994,921 (n)4,921 (n) Pan−13%1.13 · 0.70–1.82239 (n)523 (n) Oh1%0.99 · 0.65–1.50n/an/a Son (PSM)11%0.89 · 0.53–1.47case-control study Ma (PSM)9%0.91 · 0.82–1.02 Chow (PSM)19%0.81 · 0.76–0.871,280/6,7812,271/10,566 Kim (PSM)−700%8.00 · 1.07–59.616/151/20 Basheer−13%1.13 · 1.05–1.2145/14029/250 Sisinni−7%1.07 · 0.89–1.2993/253251/731 Pérez-Segura−49%1.49 · 1.20–1.8066/155183/608 Formiga (PSM)−3%1.03 · 0.94–1.131,000/3,291874/2,885 Sullerot (PSW)−10%1.10 · 0.81–1.49101/301224/746 Monserrat .. (PSM)−31%1.31 · 1.01–1.71n/an/a Gogtay−6%1.06 · 0.51–1.8912/3821/87 Campbell (PSW)3%0.97 · 0.95–1.00419 (n)20,311 (n) Lal11%0.89 · 0.82–0.974,691 (n)16,888 (n) Malik14%0.86 · 0.39–1.8015/8724/223 Abul33%0.67 · 0.47–0.9546/511201/1,176 Loucera18%0.82 · 0.74–0.922,127 (n)13,841 (n) Morrison (PSM)8%0.92 · 0.73–1.181,667 (n)1,667 (n) Ali28%0.72 · 0.51–1.03481 (n)1,164 (n) Zadeh37%0.63 · 0.30–1.29n/an/a Azizi0%1.00 · 0.53–1.8717/13117/131 Aweimer−10%1.10 · 0.90–1.3434/4474/105Intubated patients Prieto-Campo−13%1.13 · 0.86–1.48case-control study Ware (PSM)46%0.54 · 0.53–0.56population-based cohort Miele−32%1.32 · 1.04–1.68n/an/a Kurnik (ICU)−11%1.11 · 0.92–1.3433/4067/90ICU patients
Prophylaxis3%0.97 · 0.87–1.083,465/34,3325,415/85,8953% lower risk
Tau² = 0.07, I² = 93.9%, p = 0.56
All studies8%0.92 · 0.86–0.984,684/51,3427,366/109K8% lower risk
Tau² = 0.04, I² = 90.6%, p = 0.008900.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 6. Random-effects meta-analysis for mortality results.
October 2026

Aspirin COVID-19 mechanical ventilation results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment8%0.92 · 0.75–1.14263/9,254297/9,2738% lower risk
Tau² = 0.05, I² = 63.8%, p = 0.46
Prophylaxis2%0.98 · 0.93–1.022,344/13,6913,606/22,5552% lower risk
Tau² = 0.00, I² = 1.1%, p = 0.32
All studies5%0.95 · 0.85–1.052,607/22,9453,903/31,8285% lower risk
Tau² = 0.01, I² = 50.9%, p = 0.2900.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 7. Random-effects meta-analysis for ventilation.
October 2026

Aspirin COVID-19 ICU results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment3%0.97 · 0.70–1.3586/1,103215/1,2423% lower risk
Tau² = 0.11, I² = 77.7%, p = 0.88
Prophylaxis2%0.98 · 0.83–1.16363/10,184424/22,8102% lower risk
Tau² = 0.04, I² = 84.2%, p = 0.8
All studies3%0.97 · 0.84–1.11449/11,287639/24,0523% lower risk
Tau² = 0.04, I² = 80.8%, p = 0.6800.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 8. Random-effects meta-analysis for ICU admission.
October 2026

Aspirin COVID-19 hospitalization results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Late treatment17%0.83 · 0.59–1.1856/1,94567/1,93617% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.3
Prophylaxis−1%1.01 · 0.96–1.07186/2,931488/5,4861% higher risk
Tau² = 0.00, I² = 56.0%, p = 0.59
All studies−1%1.01 · 0.96–1.06242/5,020556/7,5581% higher risk
Tau² = 0.00, I² = 49.3%, p = 0.700.511.52+
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 9. Random-effects meta-analysis for hospitalization.
October 2026

Aspirin COVID-19 progression results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Early treatment19%0.81 · 0.28–2.356/1447/13619% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.71
Late treatment19%0.81 · 0.69–0.94559/4,201615/4,06019% lower risk
Tau² = 0.01, I² = 33.0%, p = 0.0064
Prophylaxis7%0.93 · 0.87–1.004,691 (n)16,888 (n)7% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.04
All studies11%0.89 · 0.82–0.96565/9,036622/21,08411% lower risk
Tau² = 0.00, I² = 25.2%, p = 0.003800.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 10. Random-effects meta-analysis for progression.
October 2026

Aspirin COVID-19 recovery results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Late treatment9%0.91 · 0.82–1.01162/7,925175/8,0939% lower risk
Tau² = 0.00, I² = 27.6%, p = 0.087
All studies9%0.91 · 0.82–1.01162/7,925175/8,0939% lower risk
Tau² = 0.00, I² = 27.6%, p = 0.08700.511.52+
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 11. Random-effects meta-analysis for recovery.
October 2026

Aspirin COVID-19 case results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Prophylaxis5%0.95 · 0.86–1.0588/1,757609/8,9925% lower risk
Tau² = 0.01, I² = 67.1%, p = 0.34
All studies5%0.95 · 0.86–1.0588/1,757609/8,9925% lower risk
Tau² = 0.01, I² = 67.1%, p = 0.3400.511.52+
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 12. Random-effects meta-analysis for cases.
October 2026

Aspirin COVID-19 viral clearance results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Late treatment−2%1.02 · 0.64–1.6124 (n)24 (n)2% higher risk
Tau² = 0.00, I² = 0.0%, p = 0.94
Prophylaxis10%0.90 · 0.82–1.0073 (n)589 (n)10% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.045
All studies9%0.91 · 0.83–1.0097 (n)613 (n)9% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.05200.511.52+
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 13. Random-effects meta-analysis for viral clearance.
October 2026

Aspirin COVID-19 peer reviewed studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Alamdari−28%1.28 · 0.67–2.43death9/5354/406 Goshua (PSM)35%0.65 · 0.42–0.98death319 (n)319 (n) Meizlish (PSM)48%0.52 · 0.34–0.81death319 (n)319 (n) Liu (PSM)75%0.25 · 0.07–0.87death2/2811/204 Mura (PSM)15%0.85 · 0.69–1.01death527 (n)527 (n) Chow47%0.53 · 0.31–0.90death26/9873/314 Haji Aghajani25%0.75 · 0.57–0.99death336 (n)655 (n) Elhadi (ICU)10%0.90 · 0.67–1.21death22/40259/425ICU patients Sahai (PSM)13%0.87 · 0.56–1.34death33/24838/248 Vahedian-Azimi22%0.78 · 0.33–1.74death13/33728/250 Abdelwahab−8%1.08 · 0.15–3.82ventilation11/316/36 Karruli (ICU)46%0.54 · 0.09–3.13death1/522/27ICU patients Al Harthi (ICU)27%0.73 · 0.56–0.97death98/176107/173ICU patients Kim (PSM)34%0.66 · 0.36–1.23death14/12423/135 Zhao43%0.57 · 0.41–0.78death121/473140/473 Horby (RCT)4%0.96 · 0.89–1.04death7,351 (n)7,541 (n)RECOVERY Mustafa44%0.56 · 0.21–1.51death4/6641/378 Bradbury (RCT)16%0.84 · 0.70–1.00death165/563170/521REMAP-CAP Chow (PSW)13%0.87 · 0.81–0.93deathpopulation-based cohort Santoro (PSM)38%0.62 · 0.42–0.92death360 (n)2,949 (n) Ghati (RCT)22%0.78 · 0.31–1.98death11/4427/219RESIST Karimpour-Razke..−123%2.23 · 1.26–3.38death39/9064/363 Eikelboom (RCT)−5%1.05 · 0.86–1.28death193/1,063186/1,056ACT inpatientCT1 Eikelboom (RCT)−9%1.09 · 0.48–2.46death12/1,94511/1,936ACT outpatient Ali (ICU)40%0.60 · 0.51–0.72death152/660202/530ICU patients Singla (RCT)57%0.43 · 0.04–3.27death3/495/49CT1 Shamsi96%0.04 · 0.00–0.58death0/1324/170 Mehrizi16%0.84 · 0.82–0.86deathpopulation-based cohort Lewandowski−70%1.70 · 1.08–2.70death430 (all patients) Vinod14%0.86 · 0.48–1.52death128 (n)248 (n) Azimi Pirsaraei−97%1.97 · 1.28–3.04death28/18450/647 Dinoi−55%1.55 · 1.05–2.30deathcase-control study
Late treatment14%0.86 · 0.79–0.93957/16,0281,521/21,11814% lower risk
Tau² = 0.02, I² = 77.9%, p = 0.00027
Holt−34%1.34 · 0.98–1.84death/ICU35/116129/573 Wang58%0.42 · 0.01–1.98death1/913/49 Lodigiani−21%1.21 · 0.73–2.01ICU17/9444/294 Yuan4%0.96 · 0.47–1.72death11/5229/131 Osborne (PSM)59%0.41 · 0.35–0.48death272/6,300661/6,300 Merzon28%0.72 · 0.53–0.99cases73/1,621589/8,856 Bejan1%0.99 · 0.61–1.63ventilation1,899 (n)7,330 (n) Mulhem−14%1.14 · 0.93–1.40death300/1,354216/1,865 Pan−13%1.13 · 0.70–1.82death239 (n)523 (n) Oh1%0.99 · 0.65–1.50deathn/an/a Son (PSM)11%0.89 · 0.53–1.47deathcase-control study Ma (PSM)9%0.91 · 0.82–1.02death Chow (PSM)19%0.81 · 0.76–0.87death1,280/6,7812,271/10,566 Kim (PSM)−700%8.00 · 1.07–59.61death6/151/20 Basheer−13%1.13 · 1.05–1.21death45/14029/250 Sisinni−7%1.07 · 0.89–1.29death93/253251/731 Pérez-Segura−49%1.49 · 1.20–1.80death66/155183/608 Formiga (PSM)−3%1.03 · 0.94–1.13death1,000/3,291874/2,885 Sullerot (PSW)−10%1.10 · 0.81–1.49death101/301224/746 Monserrat .. (PSM)−31%1.31 · 1.01–1.71deathn/an/a Levy26%0.74 · 0.49–1.10death/hosp.29/159178/690 Nimer4%0.96 · 0.69–1.33hosp.83/427136/1,721 Gogtay−6%1.06 · 0.51–1.89death12/3821/87 Campbell (PSW)3%0.97 · 0.95–1.00death419 (n)20,311 (n) Lal11%0.89 · 0.82–0.97death4,691 (n)16,888 (n) Botton−4%1.04 · 0.98–1.10death/int.population-based cohort Malik14%0.86 · 0.39–1.80death15/8724/223 Loucera18%0.82 · 0.74–0.92death2,127 (n)13,841 (n) Morrison (PSM)8%0.92 · 0.73–1.18death1,667 (n)1,667 (n) Ali28%0.72 · 0.51–1.03death481 (n)1,164 (n) Zadeh37%0.63 · 0.30–1.29deathn/an/a Azizi0%1.00 · 0.53–1.87death17/13117/131 Aweimer−10%1.10 · 0.90–1.34death34/4474/105Intubated patients Tse (PSM)67%0.33 · 0.18–0.59death/int.2,664 (all patients) Prieto-Campo−13%1.13 · 0.86–1.48deathcase-control study Sakamaki−37%1.37 · 1.31–1.44severe casepopulation-based cohort Kurnik (ICU)−11%1.11 · 0.92–1.34death33/4067/90ICU patients
Prophylaxis4%0.96 · 0.88–1.053,523/32,9316,031/98,6454% lower risk
Tau² = 0.05, I² = 92.4%, p = 0.4
All studies8%0.92 · 0.86–0.984,480/49,1037,553/119K8% lower risk
Tau² = 0.04, I² = 90.9%, p = 0.008500.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
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 and 17 show forest plots for random-effects meta-analysis of all Randomized Controlled Trials and RCT mortality results. RCT results are included in Table 1 and Table 2.
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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 biases51, and analysis of double-blind RCTs has identified extreme levels of bias52. 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 aspirin 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.
Fig. 18. For COVID-19, observational study results do not systematically differ from RCTs, RR 0.97 [0.91‑1.03] across 227 treatments56.
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]59. 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 0.93 [0.85‑1.02]. 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 see61,62.
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.
October 2026

Aspirin COVID-19 Randomized Controlled Trials

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Late treatment5%0.95 · 0.89–1.02384/11,413379/11,3225% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.16
All studies5%0.95 · 0.89–1.02384/11,557380/11,4585% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.1500.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
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.
October 2026

Aspirin COVID-19 RCT mortality results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment5%0.95 · 0.89–1.02384/11,413379/11,3225% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.16
All studies5%0.95 · 0.89–1.02384/11,413379/11,3225% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.1600.511.52+
1 CT: study uses combined treatment
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← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 17. Random-effects meta-analysis for RCT mortality 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. 19 shows a forest plot for random-effects meta-analysis of all studies after exclusions.
Alamdari, substantial unadjusted confounding by indication likely.
Aweimer, unadjusted results with no group details.
Azimi Pirsaraei, unadjusted results with no group details.
Azizi, age matching based on only two categories, matching may be very poor given the relationship between age and COVID-19 risk; inconsistent data.
Elhadi, unadjusted results with no group details.
Holt, unadjusted results with no group details.
Karimpour-Razkenari, substantial unadjusted confounding by indication likely.
Kurnik, unadjusted results with no group details.
Miele, substantial unadjusted confounding by indication possible.
Mulhem, substantial unadjusted confounding by indication likely; substantial confounding by time likely due to declining usage over the early stages of the pandemic when overall treatment protocols improved dramatically.
Mustafa, unadjusted results with no group details.
Shamsi, unadjusted results with no group details.
October 2026

Aspirin COVID-19 studies after exclusions

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment67%0.33 · 0.01–7.960/1441/13667% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.5
Husain80%0.20 · 0.01–3.55death0/113/31 Goshua (PSM)35%0.65 · 0.42–0.98death319 (n)319 (n) Meizlish (PSM)48%0.52 · 0.34–0.81death319 (n)319 (n) Liu (PSM)75%0.25 · 0.07–0.87death2/2811/204 Mura (PSM)15%0.85 · 0.69–1.01death527 (n)527 (n) Chow47%0.53 · 0.31–0.90death26/9873/314 Haji Aghajani25%0.75 · 0.57–0.99death336 (n)655 (n) Sahai (PSM)13%0.87 · 0.56–1.34death33/24838/248 Pourhoseingholi−32%1.32 · 1.02–1.71death71/290268/2,178 Vahedian-Azimi22%0.78 · 0.33–1.74death13/33728/250 Abdelwahab−8%1.08 · 0.15–3.82ventilation11/316/36 Karruli (ICU)46%0.54 · 0.09–3.13death1/522/27ICU patients Al Harthi (ICU)27%0.73 · 0.56–0.97death98/176107/173ICU patients Kim (PSM)34%0.66 · 0.36–1.23death14/12423/135 Zhao43%0.57 · 0.41–0.78death121/473140/473 Horby (RCT)4%0.96 · 0.89–1.04death7,351 (n)7,541 (n)RECOVERY Bradbury (RCT)16%0.84 · 0.70–1.00death165/563170/521REMAP-CAP Chow (PSW)13%0.87 · 0.81–0.93deathpopulation-based cohort Santoro (PSM)38%0.62 · 0.42–0.92death360 (n)2,949 (n) Ghati (RCT)22%0.78 · 0.31–1.98death11/4427/219RESIST Eikelboom (RCT)−5%1.05 · 0.86–1.28death193/1,063186/1,056ACT inpatientCT1 Eikelboom (RCT)−9%1.09 · 0.48–2.46death12/1,94511/1,936ACT outpatient Ali (ICU)40%0.60 · 0.51–0.72death152/660202/530ICU patients Aidouni (ICU)31%0.69 · 0.54–0.88death202/712165/412ICU patients Singla (RCT)57%0.43 · 0.04–3.27death3/495/49CT1 Mehrizi16%0.84 · 0.82–0.86deathpopulation-based cohort Lewandowski−70%1.70 · 1.08–2.70death430 (all patients) Vinod14%0.86 · 0.48–1.52death128 (n)248 (n) Dinoi−55%1.55 · 1.05–2.30deathcase-control study
Late treatment18%0.82 · 0.76–0.881,128/16,5951,465/21,35018% lower risk
Tau² = 0.02, I² = 73.2%, p < 0.0001
Wang58%0.42 · 0.01–1.98death1/913/49 Lodigiani−21%1.21 · 0.73–2.01ICU17/9444/294 Yuan4%0.96 · 0.47–1.72death11/5229/131 Ramos-Rincón−29%1.29 · 1.05–1.51death132/264253/526 Osborne (PSM)59%0.41 · 0.35–0.48death272/6,300661/6,300 Merzon28%0.72 · 0.53–0.99cases73/1,621589/8,856 Bejan1%0.99 · 0.61–1.63ventilation1,899 (n)7,330 (n) Reese (PSM)−61%1.61 · 1.31–1.99death4,921 (n)4,921 (n) Drew22%0.78 · 0.49–1.24progressionn/an/a Pan−13%1.13 · 0.70–1.82death239 (n)523 (n) Oh1%0.99 · 0.65–1.50deathn/an/a Son (PSM)11%0.89 · 0.53–1.47deathcase-control study Ma (PSM)9%0.91 · 0.82–1.02death Chow (PSM)19%0.81 · 0.76–0.87death1,280/6,7812,271/10,566 Kim (PSM)−700%8.00 · 1.07–59.61death6/151/20 Basheer−13%1.13 · 1.05–1.21death45/14029/250 Sisinni−7%1.07 · 0.89–1.29death93/253251/731 Pérez-Segura−49%1.49 · 1.20–1.80death66/155183/608 Formiga (PSM)−3%1.03 · 0.94–1.13death1,000/3,291874/2,885 Sullerot (PSW)−10%1.10 · 0.81–1.49death101/301224/746 Monserrat .. (PSM)−31%1.31 · 1.01–1.71deathn/an/a Levy26%0.74 · 0.49–1.10death/hosp.29/159178/690 Nimer4%0.96 · 0.69–1.33hosp.83/427136/1,721 Gogtay−6%1.06 · 0.51–1.89death12/3821/87 Campbell (PSW)3%0.97 · 0.95–1.00death419 (n)20,311 (n) Lal11%0.89 · 0.82–0.97death4,691 (n)16,888 (n) Botton−4%1.04 · 0.98–1.10death/int.population-based cohort Malik14%0.86 · 0.39–1.80death15/8724/223 Abul33%0.67 · 0.47–0.95death46/511201/1,176 Loucera18%0.82 · 0.74–0.92death2,127 (n)13,841 (n) Morrison (PSM)8%0.92 · 0.73–1.18death1,667 (n)1,667 (n) Ali28%0.72 · 0.51–1.03death481 (n)1,164 (n) Zadeh37%0.63 · 0.30–1.29deathn/an/a Tse (PSM)67%0.33 · 0.18–0.59death/int.2,664 (all patients) Prieto-Campo−13%1.13 · 0.86–1.48deathcase-control study Ware (PSM)46%0.54 · 0.53–0.56deathpopulation-based cohort Sakamaki−37%1.37 · 1.31–1.44severe casepopulation-based cohort
Prophylaxis7%0.93 · 0.84–1.033,282/36,9425,982/102K7% lower risk
Tau² = 0.08, I² = 95.6%, p = 0.17
All studies12%0.88 · 0.82–0.944,410/53,6817,448/123K12% lower risk
Tau² = 0.05, I² = 93.5%, p = 0.0003400.511.52+
1 CT: study uses combined treatment
Rotate screen for more detailsIncrease width for more details
← Aspirin
reduces risk
Aspirin
increases risk →
Fig. 19. 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.
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."75.
We analyze media coverage for the 227 treatments we cover using Altmetric76, which reports the number of ~12,000 tracked news outlets that covered each study77. Studies are considered to have received significant media coverage if they were covered by at least 0.5% of the tracked news outlets. Fig. 20, 21, and 22 show the bias toward negative results for low-cost treatments, in contrast to the opposite bias for high-profit treatments. This 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, and high-profit treatments were also more difficult to access, especially for earlier treatment which improves efficacy and minimizes community transmission.
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Fig. 20. Media was more likely to cover negative or inconclusive results for low-cost treatments, and positive results for high-profit treatments.
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Fig. 21. Mainstream media was biased against positive results for low-cost treatments.
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Fig. 22. In contrast to the results for low-cost treatments, mainstream media was biased towards positive results for high-cost treatments.
A combination of factors may have led to the media's suppression 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 banned on Twitter and YouTube.
•
FDA requires "no adequate, approved, and available alternatives"
in order to grant an EUA for novel high-profit interventions, creating a strong 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. Relatively few journalists have a strong ability to analyze clinical trials and are outnumbered by the rest.
•
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, fear, and anxieties. A negative bias may improve ratings and revenue, increasing motivation to continue watching coverage. A combination of low-cost treatments greatly reducing risk conflicts with the negative narrative.
25 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 yearsB. 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.
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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 hours78,79. 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.
Table 3. Studies of baloxavir marboxil for influenza show that early treatment is more effective.
Treatment delayResult
Post-exposure prophylaxis86% fewer cases80
<24 hours-33 hours symptoms81
24-48 hours-13 hours symptoms81
Inpatients-2.5 hours to improvement82
Fig. 23 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.
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Fig. 23. 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 variants84, for example the Gamma variant shows significantly different characteristics85-88. 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 variants89,90.
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.
The use of other treatments may significantly affect outcomes, including supplements, other medications, or other interventions such as prone positioning. Treatments may be synergistic93-117, therefore efficacy may depend strongly on combined treatments.
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.
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. 24 shows that lower hospitalization is very strongly associated with lower mortality (p < 0.0000000001). Similarly, Fig. 25 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. 26 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.
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Fig. 24. Lower hospitalization is associated with lower mortality, supporting pooled outcome analysis.
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Fig. 25. Improved recovery is associated with lower mortality, supporting pooled outcome analysis.
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Fig. 24. 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. 27 shows when treatments were found effective during the pandemic. Pooled outcomes often resulted in earlier detection of efficacy.
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Fig. 27. 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 targets119. Studies show complementary and synergistic effects with polytherapy93-117. For example, Jitobaom et al.94 shows >10x reduction in IC50 with ivermectin and niclosamide, an RCT by Said et al.101 showed the combination of nigella sativa and vitamin D was more effective than either alone, and an RCT by Wannigama et al.120 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 pressure121-128. Antigenic drift can undermine more variant-specific treatments like monoclonal antibodies and more specific antivirals. Treatment with targeted antivirals may select for escape mutations129. The efficacy of treatments varies depending on cell type130 due to differences in viral receptor expression, drug distribution and metabolism, and cell-specific mechanisms. Efficacy may also vary based on genetic variants131-141.
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
27% [24–30%]
71% [60–79%]
Late treatment
18% [16–20%]
49% [41–55%]
Prophylaxis
28% [25–30%]
90% [48–98%]
Studies where combined treatments may significantly contribute to efficacy are excluded from this meta-analysis142-145. While not reaching statistical significance, aspirin studies using polytherapy also show greater efficacy than monotherapy studies. This comparison includes combined treatment studies excluded from the rest of this paper142-145.
Polytherapy vs. monotherapy for aspirin
Monotherapy Polytherapy
Late treatment
14% [7–21%]
70% [-3–91%]
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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 results146-149.
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. 28 shows a scatter plot of results for prospective and retrospective studies. 36% of retrospective studies report a statistically significant positive effect for one or more outcomes, compared to 30% of prospective studies, consistent with a bias toward publishing positive results. The median effect size for retrospective studies is 11% improvement, compared to 13% for prospective studies, showing similar results.
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Fig. 28. 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. 29 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 < 0.05150-157. 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.
Log Risk Ratio Standard Error 1.406 1.055 0.703 0.352 0 -3 -2 -1 0 1 2 A: Simulated perfect trials p > 0.05 Log Risk Ratio Standard Error 1.433 1.074 0.716 0.358 0 -4 -3 -2 -1 0 1 2 B: Simulated perfect trials with varying treatment delay p < 0.0001
Fig. 29. 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. Aspirin for COVID-19 lacks this because it is off-patent, has multiple manufacturers, and is very low cost. In contrast, most COVID-19 aspirin 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 aspirin 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 alone93-117. 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.
2 of 79 studies combine treatments. The results of aspirin alone may differ. 2 of 7 RCTs use combined treatment. 4 other meta-analyses show significant improvements with aspirin for mortality2-4, mechanical ventilation2, and progression5.
Additional preclinical or review papers suggesting potential benefits of aspirin for COVID-19 include225-238. We have not reviewed these studies in detail.
SARS-CoV-2 infection and replication involves a complex interplay of 500+ host and viral proteins and other factors36-43, providing many therapeutic targets. Over 12,000 compounds have been predicted to reduce COVID-19 risk44, either by directly minimizing infection or replication, by supporting immune system function, or by minimizing secondary complications. Fig. 30 shows an overview of the results for aspirin in the context of multiple COVID-19 treatments, and Fig. 31 shows a plot of efficacy vs. cost for COVID-19 treatments.
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Fig. 30. Scatter plot showing results within the context of multiple COVID-19 treatments. Diamonds shows the results of random-effects meta-analysis. 0.5% of 12,000+ proposed treatments show efficacy239.
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Fig. 31. Efficacy vs. cost for COVID-19 treatments.
Significantly lower risk is seen for mortality and progression. 28 studies from 26 independent teams in 11 countries show significant benefit. Meta-analysis using the most serious outcome reported shows 8% [2‑13%] lower risk. Early treatment is more effective than late treatment.
Studies to date do not show a significant benefit for mechanical ventilation, ICU admission, or hospitalization. Bunditanukul et al. show increased risk of major bleeding. Benefit may be more likely without coadministered anticoagulants. The RECOVERY RCT shows 4% [-4‑11%] lower mortality for all patients, however when restricting to non-LMWH patients there was 17% [-4‑34%] improvement, comparable with the mortality results of all studies, 8% [2‑14%], and the 16% improvement in the REMAP-CAP RCT.
4 other meta-analyses show significant improvements with aspirin for mortality2-4, mechanical ventilation2, and progression5.
 
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 228,000 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/emeta.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/.
Retrospective 225 hospitalized patients in Egypt, showing significantly lower thromboembolic events with aspirin treatment, but no significant difference in the need for mechanical ventilation. Submit Corrections or Updates.
Retrospective 1,687 nursing home residents in the USA, showing significantly lower risk of mortality with chronic low-dose aspirin use. Low dose 81mg aspirin users had treatment ≥10 of 14 days prior to the positive COVID date, control patients had no aspirin use in the prior 14 days. Submit Corrections or Updates.
Prospective study of 1,124 COVID-19 ICU patients, showing lower mortality with aspirin treatment. Submit Corrections or Updates.
Retrospective 1,033 critical condition patients, showing lower in-hospital mortality with aspirin in PSM analysis. Patients receiving aspirin also had a higher risk of significant bleeding, although not reaching statistical significance. Authors note that the use of aspirin during an ICU stay should be tailored to each patient. Submit Corrections or Updates.
Retrospective 459 patients in Iran, 53 treated with aspirin, showing no significant difference with treatment. Submit Corrections or Updates.
Retrospective 1,645 hospitalized patients in the USA, showing lower mortality with aspirin use, without statistical significance. Submit Corrections or Updates.
Retrospective 1,190 ICU patients in Egypt, showing lower mortality with aspirin treatment. 150mg daily. Submit Corrections or Updates.
Retrospective 149 patients under invasive mechanical ventilation in Germany showing no significant difference in mortality with aspirin prophylaxis in unadjusted results. Submit Corrections or Updates.
Retrospective 831 hospitalized COVID-19 patients showing higher mortality with aspirin treatment in unadjusted results. Submit Corrections or Updates.
Retrospective 131 COVID-19 patients with aspirin use and 131 matched controls in Iran, showing no significant difference in outcomes, however age matching used only two categories, 40-60 and 60+, therefore matching may be very poor given the relationship between age and COVID-19 risk. The percentages given for the control group death/recovery outcomes do not match the reported counts. Submit Corrections or Updates.
Retrospective 390 hospitalized patients in Israel, showing higher risk of mortality with prior aspirin use. Details of the analysis are not provided. Submit Corrections or Updates.
Retrospective 9,748 COVID-19 patients in the USA showing no signficant difference with aspirin use. Submit Corrections or Updates.
Retrospective 31 million people without cardiovascular disease in France, showing no significant difference in hospitalization or combined intubation/death with low dose aspirin prophylaxis. Submit Corrections or Updates.
Late treatmentRCT · 1,084 patients · multinational · Oct 2020 – Jun 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower progression with aspirin
p = 0.018
RCT 1,557 critical patients, showing significantly lower mortality with aspirin, with 97.5% posterior probability of efficacy. Submit Corrections or Updates.
Retrospective 28,856 COVID-19 patients in the USA, showing no significant difference in mortality for chronic aspirin use vs. sporadic NSAID use. Since aspirin is available OTC and authors only tracked prescriptions, many patients classified as sporadic users may have been chronic users. Submit Corrections or Updates.
PSM retrospective 6,781 hospitalized patients ≥50 years old in the USA who were on pre-hospital antiplatelet therapy (84% aspirin), and 10,566 matched controls, showing lower mortality with treatment. Submit Corrections or Updates.
Retrospective 112,269 hospitalized COVID-19 patients in the USA, showing lower mortality with aspirin treatment. Submit Corrections or Updates.
Late treatmentRetrospective · 412 patients · USA
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and ventilation with aspirin
p = 0.02 (mortality) and p = 0.007 (ventilation)
Retrospective 412 hospitalized patients, 98 treated with aspirin, showing lower mortality, ventilation, and ICU admission with treatment. Submit Corrections or Updates.
Early treatmentRCT · 280 patients · USA · Sep 2020 – Jun 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower hospitalization with aspirin
Not statistically significant · p = 0.49
Early terminated RCT with 164 aspirin and 164 control patients in the USA with very few events, showing no significant difference with aspirin treatment for the combined endpoint of all-cause mortality, symptomatic venous or arterial thromboembolism, myocardial infarction, stroke, and hospitalization for cardiovascular or pulmonary indication. There was no mortality and no major bleeding events among participants that started treatment (there was one ITT placebo death). Submit Corrections or Updates.
Retrospective 247 non-survivors and 247 matched survivors in hospitalized COVID-19 patients in Italy showing results for several treatments. Submit Corrections or Updates.
Retrospective 2,736,091 individuals in the U.S., U.K., and Sweden, showing lower risk of hospital/clinic visits with aspirin use. Submit Corrections or Updates.
Late treatmentRCT · 3,881 patients · Canada · Aug 2020 – Feb 2022
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower progression and hospitalization
Not statistically significant · p = 0.21 (progression) and p = 0.31 (hospitalization)
Late (5.4 days) outpatient RCT showing no significant difference in outcomes with aspirin treatment. Submit Corrections or Updates.
Late treatmentRCT · 2,119 patients · multinational · Oct 2020 – Feb 2022
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
No significant difference in outcomes seen
RCT very late stage (baseline SpO2 77%) patients, showing no significant differences with rivaroxaban and aspirin treatment. Submit Corrections or Updates.
Prospective study of 465 COVID-19 ICU patients in Libya showing no significant differences with treatment. Submit Corrections or Updates.
ProphylaxisPSM retrospective · 20,641 patients · USA · Mar 2020 – May 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
No significant difference in outcomes seen
Retrospective 20,641 hospitalized patients in Spain, showing no significant difference in outcomes with existing aspirin use. Submit Corrections or Updates.
Late treatmentRCT · 661 patients · India · Jul 2020 – Jan 2021
Aspirin for COVID-19
Lower progression with aspirin
Not statistically significant · p = 0.46
RCT hospitalized patients in India, 224 treated with atorvastatin, 225 with aspirin, and 225 with both, showing lower serum interleukin-6 levels with aspirin, but no statistically significant changes in other outcomes. Low dose aspirin 75mg daily for 10 days. Submit Corrections or Updates.
ProphylaxisRetrospective · 125 patients · USA · Mar – Apr 2020
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower ventilation and ICU admission
Not statistically significant · p = 0.16 (ventilation) and p = 0.41 (ICU admission)
Retrospective 125 COVID+ hospitalized patients in the USA, showing no significant differences with aspirin prophylaxis. Submit Corrections or Updates.
Late treatmentPSM retrospective · 2,785 patients · USA
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and higher ventilation
p = 0.044 (mortality) and p = 0.037 (ventilation)
PSM retrospective 2,785 hospitalized patients in the USA, showing lower mortality and higher ventilation and ICU admission with aspirin treatment. Submit Corrections or Updates.
Retrospective 991 hospitalized patients in Iran, showing lower mortality with aspirin treatment. Submit Corrections or Updates.
Retrospective 689 hospitalized COVID-19 patients in Denmark, showing higher risk of ICU/death with aspirin use in unadjusted results subject to confounding by indication. Submit Corrections or Updates.
Late treatmentRCT · 14,892 patients · multinational · Nov 2020 – Mar 2021
Aspirin for COVID-19
Higher discharge with aspirin
p = 0.0062
RCT 14,892 late stage patients, 7,351 treated with aspirin, showing slightly improved discharge and hospitalization time, and no significant difference for mortality.

Results are limited due to low dose (150mg daily), very late treatment (9 days post symptom onset), and 96% concurrent use of low molecular weight heparin. Greater benefits were seen for non-LMWH patients, and for very late (≤7 days from onset) vs. extremely late (>7 days) treatment. For more discussion see240. Submit Corrections or Updates.
Late treatmentRetrospective · 42 patients · Bangladesh
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and improved recovery
Not statistically significant · p = 0.55 (mortality) and p = 0.4 (recovery)
Retrospective 42 patients in Bangladesh, 11 treated with aspirin, showing fewer complications with treatment. Submit Corrections or Updates.
Retrospective 478 moderate to severe hospitalized patients in Iran, showing higher mortality with aspirin treatment. Authors note confounding by indication for aspirin treatment. Submit Corrections or Updates.
Retrospective 32 ICU patients showing lower mortality with aspirin treatment, without statistical significance. Submit Corrections or Updates.
ProphylaxisPSM retrospective · 272 patients · South Korea
Aspirin for COVID-19
Retrospective database analysis of 22,660 patients tested for COVID-19 in South Korea. There was no significant difference in cases according to aspirin use. Aspirin use before COVID-19 was related to an increased death rate and aspirin use after COVID-19 was related to a higher risk of oxygen therapy.

Results for late treatment are listed separately174. Submit Corrections or Updates.
Late treatmentPSM retrospective · 259 patients · South Korea
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and higher ventilation
Not statistically significant · p = 0.22 (mortality) and p = 0.16 (ventilation)
Retrospective database analysis of 22,660 patients tested for COVID-19 in South Korea. There was no significant difference in cases according to aspirin use. Aspirin use before COVID-19 was related to an increased death rate and aspirin use after COVID-19 was related to a higher risk of oxygen therapy.

Results for prophylaxis are listed separately210. Submit Corrections or Updates.
Retrospective 130 elderly (≥70 years) critically ill COVID-19 patients showing no significant difference in long-term mortality with aspirin usage. Submit Corrections or Updates.
ProphylaxisRetrospective · 21,579 patients · USA · Feb 2020 – Sep 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and ICU admission
p = 0.01 (mortality) and p < 0.0001 (ICU admission)
Retrospective 21,579 hospitalized COVID-19 patients mostly in the USA, showing lower risk of mortality and severity with existing aspirin use. Submit Corrections or Updates.
Retrospective 849 COVID-19+ patients in skilled nursing homes, showing lower risk of combined hospitalization/death with aspirin prophylaxis, not reaching statistical significance. Submit Corrections or Updates.
Retrospective 430 hospitalized COVID-19 patients with type 2 diabetes in Poland showing lower mortality with metformin and higher mortality with remdesivir, convalescent plasma, and aspirin in univariable analysis. These results were not statistically significant except for aspirin, and no baseline information per treatment is provided to assess confounding. Submit Corrections or Updates.
Retrospective PSM analysis of 232 hospitalized patients, 28 treated with aspirin, showing lower mortality with treatment. There was no significant difference in viral clearance. Submit Corrections or Updates.
Retrospective 388 hospitalized COVID-19 patients in Italy showing higher use of aspirin in ICU patients, without statistical significance. Submit Corrections or Updates.
Retrospective 15,968 COVID-19 hospitalized patients in Spain, showing lower mortality with existing use of several medications including metformin, HCQ, azithromycin, aspirin, vitamin D, vitamin C, and budesonide. Since only hospitalized patients are included, results do not reflect different probabilities of hospitalization across treatments. Submit Corrections or Updates.
UK Biobank retrospective 77,271 patients aged 50-86, showing no significant differences with aspirin use. Matching lead to different results for the gender vs. overall analysis, for example the overall result for cases was OR 1.07, however both gender results are lower OR 0.97 and 1.02. Submit Corrections or Updates.
ProphylaxisRetrospective · 310 patients · USA · Mar – Dec 2020
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower ICU admission and ARDS
Not statistically significant · p = 0.17 (ICU admission) and p = 0.39 (ARDS)
Retrospective 539 patients in the USA, showing lower mortality, ICU admission, and ARDS with aspirin treatment, without statistical significance. Submit Corrections or Updates.
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.

Submit Corrections or Updates.
Retrospective 638 matched hospitalized patients in the USA, 319 treated with aspirin, showing lower mortality with treatment. Submit Corrections or Updates.
ProphylaxisRetrospective · 10,477 patients · Israel
Aspirin for COVID-19
Fewer cases and faster viral clearance
p = 0.041 (Fewer cases) and p = 0.045 (viral clearance)
Retrospective 10,477 patients in Israel, showing lower risk of COVID-19 cases with existing aspiring use. Submit Corrections or Updates.
Retrospective 485,779 osteoarthritis patients in the US showing lower mortality with non-aspirin NSAIDs and celecoxib, and higher mortality with aspirin. Aspirin was associated with higher hospitalization in COVID-positive and COVID-negative patients. Comparison of the COVID-positive and COVID-negative results suggests significant residual confounding. Submit Corrections or Updates.
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. Submit Corrections or Updates.
ProphylaxisPSM retrospective · 13,585 patients · USA · Mar 2020 – Mar 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Higher hospitalization with aspirin
p = 0.045
Retrospective 13,585 COVID+ patients in the USA, showing higher hospitalization with aspirin use, and no significant difference for mortality, ventilation, and ICU admission. Submit Corrections or Updates.
Retrospective database analysis of 3,219 hospitalized patients in the USA. Very different results in the time period analysis (Table S2), and results significantly different to other studies for the same medications (e.g., heparin OR 3.06 [2.44-3.83]) suggest significant confounding by indication and confounding by time. Submit Corrections or Updates.
Late treatmentPSM retrospective · 1,054 patients · multinational
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Aspirin
reduces risk
Aspirin
increases risk →
Lower mortality with aspirin
Not statistically significant · p = 0.081
PSM retrospective TriNetX database analysis of 1,379 severe COVID-19 patients requiring respiratory support, showing lower mortality with aspirin (not reaching statistical significance) and famotidine, and improved results from the combination of both. Submit Corrections or Updates.
Retrospective 444 hospitalized patients in Pakistan, showing lower mortality with aspirin treatment in unadjusted results, not reaching statistical significance. Submit Corrections or Updates.
ProphylaxisRetrospective · 2,148 patients · Jordan · Mar – Jul 2021
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Aspirin
reduces risk
Aspirin
increases risk →
Higher severe cases with aspirin
Not statistically significant · p = 0.28
Retrospective 2,148 COVID-19 recovered patients in Jordan, showing no significant differences in the risk of severity and hospitalization with aspirin prophylaxis. Submit Corrections or Updates.
Retrospective database analysis of 328,374 adults in South Korea, showing lower risk of COVID-19 cases with aspirin use, but no difference in mortality for COVID-19 patients. Submit Corrections or Updates.
Retrospective PSM analysis of pre-existing aspirin use in the USA, showing lower mortality with treatment. Submit Corrections or Updates.
Retrospective 762 COVID+ hospitalized patients in the USA, 239 on antiplatelet medication (199 aspirin), showing no significant differences in outcomes.

For more discussion see241. Submit Corrections or Updates.
Prospective study of 2,468 hospitalized COVID-19 patients in Iran, showing higher mortality with aspirin treatment. IR.MUQ.REC.1399.013. Submit Corrections or Updates.
Population-based case-control study of 86,602 people in Spain, shower lower risk of COVID-19 cases with low-dose aspirin, but no significant difference for severity, hospitalization, or mortality. Submit Corrections or Updates.
Retrospective 770 COVID-19 patients with cancer, showing increased mortality with aspirin use in unadjusted results. Submit Corrections or Updates.
Retrospective 790 hospitalized type 2 diabetes patients ≥80 years old in Spain, showing higher mortality with existing aspirin use. Submit Corrections or Updates.
N3C retrospective 250,533 patients showing significantly higher mortality with aspirin use. Note that aspirin results were not included in the journal version or v2 of this preprint. Submit Corrections or Updates.
PSM retrospective 1,994 PCR+ patients in the USA, not showing a significant difference in mortality with aspirin treatment. Submit Corrections or Updates.
Retrospective 650,317 COVID-19 patients in Japan showing higher risk of severe COVID-19 with low-dose apirin use. Although cardiovascular disease should have been adjusted for (details of adjustments are not provided), there may be significant residual confounding because aspirin use might indicate more severe or complex cardiovascular issues not fully captured by the adjustment. Submit Corrections or Updates.
HOPE-COVID-19 PSM retrospective 7,824 patients, comparing prophylactic anticoagulation with and without additional treatment with aspirin in hospitalized patients, showing lower mortality with aspirin treatment. Submit Corrections or Updates.
Retrospective 183 hospitalized pediatric COVID-19 patients in Iran, showing no significant difference in mortality with aspirin in unadjusted results. Submit Corrections or Updates.
Late treatmentRCT · NCT04410328 · 98 patients · USA · Oct 2020 – Apr 2021
Aspirin for COVID-19
RCT 98 hospitalized patients in the USA, 49 treated with aspirin and dipyridamole, showing improved results with treatment, but without statistical significance. Submit Corrections or Updates.
Retrospective 984 COVID-19 patients, 253 taking aspirin prior to admission, showing lower risk of respiratory support upgrade with treatment. Submit Corrections or Updates.
ProphylaxisPSM retrospective · 21,669 patients · South Korea
Aspirin for COVID-19
No significant difference in outcomes seen
PSM retrospective case control study in South Korea, showing a trend towards lower mortality, but no significant differences with aspirin use. Submit Corrections or Updates.
ProphylaxisRetrospective · 1,047 patients · multinational · Mar – Dec 2020
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Higher ICU admission and longer hospitalization
p = 0.007 (ICU admission) and p = 0.024 (hospitalization)
Retrospective 1,047 pneumonia patients in 5 COVID-19 geriatric units in France and Switzerland, significantly higher ICU admission and longer hospital stays with existing aspirin treatment. Numbers in this study appear to be inconsistent, for example the abstract says 147 of 301 aspirin patients died, shown as 34.3%, while Table 1 shows 104 of 301 (34.6%). Submit Corrections or Updates.
PSM retrospective 2,664 COVID-19 hospitalized patients receiving steroids/antiviral therapy in Hong Kong, showing lower risk of combined death/intubation with aspirin use. Submit Corrections or Updates.
Late treatmentRetrospective · 587 patients · Iran
Aspirin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
00.511.52+
← Aspirin
reduces risk
Aspirin
increases risk →
Lower mortality with aspirin
Not statistically significant · p = 0.56
Retrospective 587 COVID+ hospitalized patients in Iran, showing no significant differences in outcomes with aspirin treatment. Submit Corrections or Updates.
Late treatmentRetrospective · 376 patients · USA · Mar – Oct 2020
Aspirin for COVID-19
Lower ventilation with aspirin
Not statistically significant · p = 0.24
Retrospective 376 hospitalized COVID-19 patients in the United States showing no significant differences with aspirin. Mortality, mechanical ventilation, and hypoxia were lower with treatment, without statistical significance. Submit Corrections or Updates.
Retrospective 58 multiple myeloma COVID-19 patients in the USA, showing no significant difference with aspirin treatment. Submit Corrections or Updates.
PSM retrospective 334,374 COVID-19 patients showing decreased risk of venous thromboembolism, including pulmonary embolism and deep vein thrombosis, but increased risk of arterial thromboembolic disorders, including ischemic stroke and acute ischemic heart disease, with aspirin use prior to COVID-19 diagnosis. The increased risk of arterial disease may be associated with preexisting cardiovascular disease for which aspirin was already prescribed. All cause mortality was lower in the aspirin group, however authors do not discuss this result. Submit Corrections or Updates.
Retrospective 183 hospitalized patients in China, 52 taking low-dose aspirin prior to hospitalization, showing no significant difference with treatment. Submit Corrections or Updates.
Retrospective 4,017 coronary artery disease patients hospitalized for COVID-19 in the USA, showing no significant difference in outcomes with low dose aspirin use. Submit Corrections or Updates.
Retrospective 2,070 hospitalized patients in the USA, showing lower mortality with aspirin treatment. Submit Corrections or Updates.
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 aspirin 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 aspirin 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. 32. 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 reduction242. 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 PythonMeta243 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 1247. 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 (3.14.8) with scipy (1.18.1), pythonmeta (1.26), numpy (2.5.3), 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.
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 reliability255. 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 issues257. Axfors et al. use RoB 2 to classify Horby (B) 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 harmC. Hempenius et al. use ROBINS-I to classify 33 studies for HCQ. The two rated as having the lowest risk of bias253,254 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 factorsD.
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 effective78,79.
This is a living analysis and is updated regularly. Submit updates or corrections with the form below. 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 the bottom of this page.
A summary of study results is below. Please submit updates and corrections at https://c19early.org/emeta.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.
Connors, 10/11/2021, Double Blind Randomized Controlled Trial, placebo-controlled, USA, peer-reviewed, 27 authors, study period September 2020 - June 2021, trial NCT04498273 (history) (ACTIV-4B). risk of hospitalization, 67.3% lower, RR 0.33, p = 0.49, treatment 0 of 144 (0.0%), control 1 of 136 (0.7%), NNT 136, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm), hospitalization for cardiovascular or pulmonary indication, suspected, started treatment.
risk of progression, 19.0% lower, RR 0.81, p = 0.78, treatment 6 of 144 (4.2%), control 7 of 136 (5.1%), NNT 102, acute medical event, suspected, started treatment.
risk of progression, 5.6% lower, RR 0.94, p = 1.00, treatment 1 of 144 (0.7%), control 1 of 136 (0.7%), NNT 2448, combined endpoint of all-cause mortality, symptomatic venous or arterial thromboembolism, myocardial infarction, stroke, and hospitalization for cardiovascular or pulmonary indication, suspected, started treatment, primary outcome.
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.
Abdelwahab, 7/30/2021, retrospective, Egypt, peer-reviewed, 17 authors. risk of mechanical ventilation, 7.8% higher, RR 1.08, p = 0.93, treatment 11 of 31 (35.5%), control 6 of 36 (16.7%), adjusted per study, odds ratio converted to relative risk.
Aidouni, 11/30/2022, prospective, Morocco, preprint, mean age 64.0, 6 authors, study period March 2020 - March 2022. risk of death, 30.9% lower, HR 0.69, p = 0.003, treatment 202 of 712 (28.4%), control 165 of 412 (40.0%), NNT 8.6, adjusted per study, multivariable, Cox proportional hazards.
risk of mechanical ventilation, 9.6% lower, RR 0.90, p = 0.33, treatment 189 of 712 (26.5%), control 121 of 412 (29.4%), NNT 35.
Al Harthi, 9/3/2021, retrospective, propensity score matching, Saudi Arabia, peer-reviewed, 21 authors. risk of death, 27.0% lower, HR 0.73, p = 0.03, treatment 98 of 176 (55.7%), control 107 of 173 (61.8%), adjusted per study, in-hospital mortality, multivariable Cox proportional hazards.
risk of death, 14.0% lower, HR 0.86, p = 0.30, treatment 95 of 176 (54.0%), control 97 of 175 (55.4%), adjusted per study, day 30, multivariable Cox proportional hazards.
ICU time, 5.3% lower, relative time 0.95, p = 0.54, treatment median 9.0 IQR 11.0 n=176, control median 9.5 IQR 11.0 n=175.
Alamdari, 9/9/2020, retrospective, Iran, peer-reviewed, 14 authors, average treatment delay 5.72 days, excluded in exclusion analyses: substantial unadjusted confounding by indication likely. risk of death, 27.7% higher, RR 1.28, p = 0.52, treatment 9 of 53 (17.0%), control 54 of 406 (13.3%).
Ali (B), 10/31/2022, retrospective, Egypt, peer-reviewed, 3 authors. risk of death, 39.6% lower, RR 0.60, p < 0.001, treatment 152 of 660 (23.0%), control 202 of 530 (38.1%), NNT 6.6.
risk of ARDS, 37.4% lower, RR 0.63, p = 0.001, treatment 74 of 660 (11.2%), control 95 of 530 (17.9%), NNT 15.
Azimi Pirsaraei, 8/13/2024, retrospective, Iran, peer-reviewed, mean age 57.2, 5 authors, study period 20 March, 2020 - 20 June, 2020, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 96.9% higher, RR 1.97, p = 0.002, treatment 28 of 184 (15.2%), control 50 of 647 (7.7%).
Bradbury, 3/22/2022, Randomized Controlled Trial, multiple countries, peer-reviewed, 73 authors, study period 30 October, 2020 - 23 June, 2021, trial NCT02735707 (history) (REMAP-CAP). risk of death, 16.0% lower, HR 0.84, p = 0.05, treatment 165 of 563 (29.3%), control 170 of 521 (32.6%), NNT 30, inverted to make HR<1 favor treatment, Kaplan-Meier, day 90.
risk of no hospital discharge, 16.9% lower, RR 0.83, p = 0.08, treatment 161 of 563 (28.6%), control 167 of 521 (32.1%), NNT 29, adjusted per study, inverted to make RR<1 favor treatment, odds ratio converted to relative risk.
risk of progression, 21.0% lower, RR 0.79, p = 0.02, treatment 204 of 563 (36.2%), control 212 of 521 (40.7%), adjusted per study, odds ratio converted to relative risk, combined death/thrombosis.
risk of progression, 4.8% lower, OR 0.95, p = 0.67, treatment 563, control 521, adjusted per study, inverted to make OR<1 favor treatment, support-free days, primary outcome, RR approximated with OR.
Chow, 3/24/2022, retrospective, USA, peer-reviewed, median age 63.0, 89 authors. risk of death, 13.5% lower, RR 0.87, p < 0.001, treatment 1,410 of 13,795 (10.2%), control 11,577 of 98,275 (11.8%), NNT 64, adjusted per study, odds ratio converted to relative risk, propensity score weighting.
Chow (B), 4/1/2021, retrospective, USA, peer-reviewed, 38 authors. risk of death, 47.0% lower, HR 0.53, p = 0.02, treatment 26 of 98 (26.5%), control 73 of 314 (23.2%), adjusted per study, Cox proportional hazards.
risk of mechanical ventilation, 44.0% lower, HR 0.56, p = 0.007, treatment 35 of 98 (35.7%), control 152 of 314 (48.4%), NNT 7.9, adjusted per study, Cox proportional hazards.
risk of ICU admission, 43.0% lower, HR 0.57, p = 0.007, treatment 38 of 98 (38.8%), control 160 of 314 (51.0%), NNT 8.2, adjusted per study, Cox proportional hazards.
Dinoi, 2/20/2025, retrospective, Italy, peer-reviewed, 11 authors, study period 17 March, 2020 - 15 June, 2021. risk of death, 54.9% higher, OR 1.55, p = 0.03, treatment 82 of 247 (33.2%) cases, 60 of 247 (24.3%) controls, case control OR.
Eikelboom, 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, trial NCT04324463 (history) (ACT outpatient). risk of death, 9.0% higher, HR 1.09, p = 0.84, treatment 12 of 1,945 (0.6%), control 11 of 1,936 (0.6%).
risk of progression, 20.0% lower, HR 0.80, p = 0.21, treatment 59 of 1,945 (3.0%), control 73 of 1,936 (3.8%), NNT 136, major thrombosis, hospitalisation, or death, primary outcome.
risk of hospitalization, 17.0% lower, HR 0.83, p = 0.31, treatment 56 of 1,945 (2.9%), control 67 of 1,936 (3.5%), NNT 172.
Eikelboom (B), 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, this trial uses multiple treatments in the treatment arm (combined with rivaroxaban) - results of individual treatments may vary, trial NCT04324463 (history) (ACT inpatient). risk of death, 5.0% higher, HR 1.05, p = 0.66, treatment 193 of 1,063 (18.2%), control 186 of 1,056 (17.6%).
risk of progression, 8.0% lower, HR 0.92, p = 0.32, treatment 281 of 1,063 (26.4%), control 300 of 1,056 (28.4%), NNT 51, major thrombosis, high-flow oxygen, ventilation, or death.
risk of progression, 11.0% lower, HR 0.89, p = 0.27, treatment 191 of 1,063 (18.0%), control 210 of 1,056 (19.9%), NNT 52, high-flow oxygen or ventilation.
Elhadi, 4/30/2021, prospective, Libya, peer-reviewed, 21 authors, study period 29 May, 2020 - 30 December, 2020, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 9.7% lower, RR 0.90, p = 0.50, treatment 22 of 40 (55.0%), control 259 of 425 (60.9%), NNT 17.
Ghati, 7/9/2022, Randomized Controlled Trial, India, peer-reviewed, 14 authors, study period 28 July, 2020 - 27 January, 2021, average treatment delay 6.0 days, trial CTRI/2020/07/026791 (RESIST). risk of death, 22.1% lower, RR 0.78, p = 0.62, treatment 11 of 442 (2.5%), control 7 of 219 (3.2%), NNT 141, aspirin and aspirin/atorvastatin vs. control, modified intention-to-treat.
risk of death, 57.5% lower, RR 0.42, p = 0.22, treatment 3 of 221 (1.4%), control 7 of 219 (3.2%), NNT 54, aspirin vs. control, modified intention-to-treat.
risk of mechanical ventilation, 9.2% lower, RR 0.91, p = 0.80, treatment 11 of 442 (2.5%), control 6 of 219 (2.7%), NNT 398, aspirin and aspirin/atorvastatin vs. control, modified intention-to-treat.
risk of mechanical ventilation, 50.5% lower, RR 0.50, p = 0.34, treatment 3 of 221 (1.4%), control 6 of 219 (2.7%), NNT 72, aspirin vs. control, modified intention-to-treat.
risk of progression, 30.0% lower, HR 0.70, p = 0.46, treatment 11 of 442 (2.5%), control 7 of 219 (3.2%), NNT 141, aspirin and aspirin/atorvastatin vs. control, Cox proportional hazards, modified intention-to-treat, primary outcome.
risk of progression, 60.0% lower, HR 0.40, p = 0.18, treatment 3 of 221 (1.4%), control 7 of 219 (3.2%), NNT 54, aspirin vs. control, Cox proportional hazards, modified intention-to-treat, primary outcome.
Goshua, 11/5/2020, retrospective, USA, peer-reviewed, 15 authors. risk of death, 35.0% lower, OR 0.65, p = 0.04, treatment 319, control 319, propensity score matching, RR approximated with OR.
risk of mechanical ventilation, 49.0% higher, OR 1.49, p = 0.04, treatment 319, control 319, propensity score matching, RR approximated with OR.
risk of ICU admission, 45.0% higher, OR 1.45, p = 0.02, treatment 319, control 319, propensity score matching, RR approximated with OR.
Haji Aghajani, 4/29/2021, retrospective, Iran, peer-reviewed, 7 authors. risk of death, 24.7% lower, HR 0.75, p = 0.04, treatment 336, control 655, adjusted per study, Cox proportional hazards, RR approximated with OR.
Horby, 11/18/2021, Randomized Controlled Trial, multiple countries, peer-reviewed, 35 authors, study period 1 November, 2020 - 21 March, 2021, average treatment delay 9.0 days, RECOVERY trial. risk of death, 4.0% lower, RR 0.96, p = 0.35, treatment 7,351, control 7,541, day 28.
risk of death, 17.0% lower, RR 0.83, p = 0.35, treatment 7,351, control 7,541, non-LMWH, day 28.
risk of mechanical ventilation, 5.0% lower, RR 0.95, p = 0.32, treatment 7,351, control 7,541, day 28.
risk of no hospital discharge, 5.7% lower, RR 0.94, p = 0.006, treatment 7,351, control 7,541, inverted to make RR<1 favor treatment, day 28.
risk of no hospital discharge, 16.0% lower, RR 0.84, p = 0.04, treatment 7,351, control 7,541, inverted to make RR<1 favor treatment, non-LMWH, day 28.
Husain, 10/31/2020, retrospective, Bangladesh, preprint, 4 authors. risk of death, 80.3% lower, RR 0.20, p = 0.55, treatment 0 of 11 (0.0%), control 3 of 31 (9.7%), NNT 10, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
risk of no recovery, 64.8% lower, RR 0.35, p = 0.40, treatment 1 of 11 (9.1%), control 8 of 31 (25.8%), NNT 6.0.
complications, 95.8% lower, RR 0.04, p = 0.001, treatment 0 of 11 (0.0%), control 17 of 31 (54.8%), NNT 1.8, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
Karimpour-Razkenari, 10/3/2022, retrospective, Iran, peer-reviewed, median age 58.5, 9 authors, study period 23 February, 2020 - 23 May, 2020, excluded in exclusion analyses: substantial unadjusted confounding by indication likely. risk of death, 123.2% higher, RR 2.23, p = 0.008, treatment 39 of 90 (43.3%), control 64 of 363 (17.6%), adjusted per study, inverted to make RR<1 favor treatment, odds ratio converted to relative risk, multivariable.
Karruli, 9/1/2021, retrospective, Italy, peer-reviewed, 13 authors, study period March 2020 - May 2020. risk of death, 46.3% lower, RR 0.54, p = 0.63, treatment 1 of 5 (20.0%), control 22 of 27 (81.5%), NNT 1.6, adjusted per study, odds ratio converted to relative risk, multivariable.
Kim, 9/4/2021, retrospective, propensity score matching, South Korea, peer-reviewed, 7 authors. risk of death, 33.7% lower, RR 0.66, p = 0.22, treatment 14 of 124 (11.3%), control 23 of 135 (17.0%), NNT 17, PSM.
risk of mechanical ventilation, 102.2% higher, RR 2.02, p = 0.16, treatment 13 of 124 (10.5%), control 7 of 135 (5.2%), PSM.
risk of ICU admission, 90.5% higher, RR 1.91, p = 0.36, treatment 7 of 124 (5.6%), control 4 of 135 (3.0%), PSM.
Lewandowski, 3/7/2024, retrospective, Poland, peer-reviewed, 15 authors. risk of death, 70.3% higher, OR 1.70, p = 0.02, RR approximated with OR.
Liu, 2/12/2021, retrospective, propensity score matching, China, peer-reviewed, 8 authors. risk of death, 75.0% lower, HR 0.25, p = 0.03, treatment 2 of 28 (7.1%), control 11 of 204 (5.4%), adjusted per study, 60 days, KM, PSM.
risk of death, 81.0% lower, HR 0.19, p = 0.02, treatment 1 of 28 (3.6%), control 9 of 204 (4.4%), adjusted per study, 30 days, KM, PSM.
time to viral-, 1.9% higher, relative time 1.02, p = 0.94, treatment 24, control 24, PSM.
Mehrizi, 12/18/2023, retrospective, Iran, peer-reviewed, 10 authors, study period 1 February, 2020 - 20 March, 2022. risk of death, 16.0% lower, OR 0.84, p < 0.001, RR approximated with OR.
Meizlish, 1/21/2021, retrospective, propensity score matching, USA, peer-reviewed, 22 authors. risk of death, 47.8% lower, HR 0.52, p = 0.004, treatment 319, control 319, PSM.
Mura, 3/31/2021, retrospective, database analysis, multiple countries, peer-reviewed, 6 authors. risk of death, 15.4% lower, RR 0.85, p = 0.08, treatment 527, control 527, odds ratio converted to relative risk, aspirin only, control prevalence approximated with treatment prevalence, propensity score matching.
risk of death, 37.3% lower, RR 0.63, p = 0.001, treatment 305, control 305, odds ratio converted to relative risk, famotidine and aspirin, control prevalence approximated with treatment prevalence, propensity score matching.
Mustafa, 12/29/2021, retrospective, Pakistan, peer-reviewed, 7 authors, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 44.1% lower, RR 0.56, p = 0.28, treatment 4 of 66 (6.1%), control 41 of 378 (10.8%), NNT 21.
Pourhoseingholi, 5/26/2021, prospective, Iran, preprint, mean age 57.9, 11 authors, study period 2 February, 2020 - 20 July, 2020, average treatment delay 7.4 days. risk of death, 32.0% higher, HR 1.32, p = 0.04, treatment 71 of 290 (24.5%), control 268 of 2,178 (12.3%), adjusted per study, multivariable, Cox proportional hazards.
Sahai, 5/19/2021, retrospective, propensity score matching, USA, peer-reviewed, 18 authors. risk of death, 13.2% lower, RR 0.87, p = 0.53, treatment 33 of 248 (13.3%), control 38 of 248 (15.3%), NNT 50.
Santoro, 6/22/2022, retrospective, propensity score matching, multivariable, multiple countries, peer-reviewed, 31 authors, study period 16 January, 2020 - 30 May, 2020. risk of death, 38.0% lower, HR 0.62, p = 0.02, treatment 360, control 2,949.
Shamsi, 7/17/2023, retrospective, Iran, peer-reviewed, 4 authors, study period 1 March, 2020 - 1 August, 2021, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 96.3% lower, RR 0.04, p = 0.22, treatment 0 of 13 (0.0%), control 24 of 170 (14.1%), NNT 7.1, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
Singla, 1/30/2023, Randomized Controlled Trial, USA, peer-reviewed, 26 authors, study period 1 October, 2020 - 30 April, 2021, this trial uses multiple treatments in the treatment arm (combined with dipyridamole) - results of individual treatments may vary, trial NCT04410328 (history). risk of death, 57.4% lower, RR 0.43, p = 0.44, treatment 3 of 49 (6.1%), control 5 of 49 (10.2%), adjusted per study, odds ratio converted to relative risk, multivariable, day 28.
risk of death, 15.0% lower, OR 0.85, p = 0.87, treatment 49, control 49, adjusted per study, multivariable, day 14, RR approximated with OR.
risk of mechanical ventilation, 20.0% lower, RR 0.80, p = 1.00, treatment 4 of 49 (8.2%), control 5 of 49 (10.2%), NNT 49.
risk of ICU admission, 28.6% lower, RR 0.71, p = 0.76, treatment 5 of 49 (10.2%), control 7 of 49 (14.3%), NNT 25.
risk of progression, 33.3% lower, RR 0.67, p = 0.74, treatment 4 of 49 (8.2%), control 6 of 49 (12.2%), NNT 24, day 28.
risk of progression, 76.3% lower, RR 0.24, p = 0.22, treatment 4 of 49 (8.2%), control 7 of 49 (14.3%), odds ratio converted to relative risk, respiratory failure, day 28.
risk of progression, 44.4% lower, RR 0.56, p = 0.39, treatment 5 of 49 (10.2%), control 9 of 49 (18.4%), NNT 12, AKI.
risk of progression, 85.7% lower, RR 0.14, p = 0.24, treatment 0 of 49 (0.0%), control 3 of 49 (6.1%), NNT 16, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm), DIC.
risk of progression, 25.0% lower, RR 0.75, p = 0.62, treatment 9 of 49 (18.4%), control 12 of 49 (24.5%), NNT 16, liver dysfunction.
Vahedian-Azimi, 7/20/2021, retrospective, Iran, peer-reviewed, 9 authors. risk of death, 21.9% lower, RR 0.78, p = 0.56, treatment 13 of 337 (3.9%), control 28 of 250 (11.2%), adjusted per study, odds ratio converted to relative risk, multivariable, primary outcome.
risk of ICU admission, 10.5% higher, RR 1.10, p = 0.67, treatment 36 of 337 (10.7%), control 44 of 250 (17.6%), adjusted per study, odds ratio converted to relative risk, multivariable.
Vinod, 6/24/2024, retrospective, USA, peer-reviewed, mean age 66.8, 8 authors, study period March 2020 - October 2020. risk of death, 14.4% lower, OR 0.86, p = 0.61, treatment 128, control 248, adjusted per study, multivariable, RR approximated with OR.
risk of mechanical ventilation, 30.3% lower, OR 0.70, p = 0.24, treatment 128, control 248, adjusted per study, multivariable, RR approximated with OR.
hypoxia, 39.6% lower, OR 0.60, p = 0.0497, treatment 128, control 248, adjusted per study, multivariable, RR approximated with OR.
readmisson, 5.8% higher, OR 1.06, p = 0.88, treatment 128, control 248, adjusted per study, multivariable, RR approximated with OR.
DVT/PE, 17.7% lower, OR 0.82, p = 0.77, treatment 128, control 248, adjusted per study, multivariable, RR approximated with OR.
Zhao, 10/1/2021, retrospective, USA, peer-reviewed, 6 authors. risk of death, 43.0% lower, HR 0.57, p < 0.001, treatment 121 of 473 (25.6%), control 140 of 473 (29.6%), adjusted per study, PSM.
risk of death, 28.0% lower, HR 0.72, p = 0.03, treatment 473, control 1,597, adjusted per study, multivariable.
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.
Abul, 8/4/2022, retrospective, USA, preprint, mean age 72.3, 10 authors, study period 13 December, 2020 - 18 September, 2021. risk of death, 33.0% lower, HR 0.67, p = 0.03, treatment 46 of 511 (9.0%), control 201 of 1,176 (17.1%), Cox proportional hazards, day 56.
risk of death, 40.0% lower, HR 0.60, p = 0.01, treatment 33 of 511 (6.5%), control 154 of 1,176 (13.1%), Cox proportional hazards, day 30.
risk of hospitalization, 20.0% lower, HR 0.80, p = 0.13, treatment 103 of 511 (20.2%), control 352 of 1,176 (29.9%), Cox proportional hazards.
Ali (C), 11/19/2022, retrospective, USA, peer-reviewed, 8 authors. risk of death, 28.0% lower, HR 0.72, p = 0.07, treatment 481, control 1,164, Cox proportional hazards.
Aweimer, 3/29/2023, retrospective, Germany, peer-reviewed, median age 67.0, 19 authors, study period 1 March, 2020 - 31 August, 2021, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 9.6% higher, RR 1.10, p = 0.43, treatment 34 of 44 (77.3%), control 74 of 105 (70.5%).
Azizi, 2/17/2023, retrospective, Iran, peer-reviewed, 6 authors, excluded in exclusion analyses: age matching based on only two categories, matching may be very poor given the relationship between age and COVID-19 risk; inconsistent data. risk of death, no change, RR 1.00, p = 1.00, treatment 17 of 131 (13.0%), control 17 of 131 (13.0%).
Basheer, 10/2/2021, retrospective, Israel, peer-reviewed, 4 authors. risk of death, 13.0% higher, RR 1.13, p < 0.001, treatment 45 of 140 (32.1%), control 29 of 250 (11.6%), adjusted per study, odds ratio converted to relative risk, group sizes approximated (only percentages provided).
Bejan, 2/28/2021, retrospective, USA, peer-reviewed, mean age 42.0, 6 authors. risk of mechanical ventilation, 1.0% lower, OR 0.99, p = 0.97, treatment 1,899, control 7,330, adjusted per study, RR approximated with OR.
Botton, 6/17/2022, retrospective, France, peer-reviewed, 7 authors. risk of death/intubation, 4.0% higher, HR 1.04, p = 0.18, Cox proportional hazards.
risk of hospitalization, 3.0% higher, HR 1.03, p = 0.046, Cox proportional hazards.
Campbell, 5/5/2022, retrospective, USA, peer-reviewed, 4 authors, study period 2 March, 2020 - 14 December, 2020. risk of death, 3.0% lower, OR 0.97, p = 0.06, treatment 419, control 20,311, adjusted per study, propensity score weighting, multivariable, day 60, RR approximated with OR.
risk of death, 2.0% lower, OR 0.98, p = 0.10, treatment 419, control 20,311, adjusted per study, propensity score weighting, multivariable, day 30, RR approximated with OR.
Chow (C), 8/29/2021, retrospective, propensity score matching, USA, peer-reviewed, 12 authors. risk of death, 19.0% lower, HR 0.81, p < 0.005, treatment 1,280 of 6,781 (18.9%), control 2,271 of 10,566 (21.5%), NNT 38, adjusted per study, Kaplan Meier.
risk of mechanical ventilation, 2.8% lower, HR 0.97, p = 0.21, treatment 2,122 of 6,781 (31.3%), control 3,403 of 10,566 (32.2%), NNT 109.
Drew, 5/2/2021, retrospective, multiple countries, preprint, 25 authors, study period 24 March, 2020 - 8 May, 2020. risk of progression, 22.0% lower, HR 0.78, p = 0.30, adjusted per study, seen in hospital/clinic, comorbidity and symptom adjusted, multivariable.
risk of case, 3.0% higher, HR 1.03, p = 0.80, adjusted per study, comorbidity and symptom adjusted, multivariable.
Formiga, 11/29/2021, retrospective, USA, peer-reviewed, 24 authors, study period 1 March, 2020 - 1 May, 2021. risk of death, 3.4% higher, RR 1.03, p = 0.48, treatment 1,000 of 3,291 (30.4%), control 874 of 2,885 (30.3%), odds ratio converted to relative risk, propensity score matching.
risk of mechanical ventilation, 3.2% higher, RR 1.03, p = 0.75, treatment 213 of 3,291 (6.5%), control 181 of 2,885 (6.3%), propensity score matching.
risk of ICU admission, 4.2% higher, RR 1.04, p = 0.65, treatment 283 of 3,291 (8.6%), control 238 of 2,885 (8.2%), propensity score matching.
Gogtay, 3/9/2022, retrospective, USA, peer-reviewed, 4 authors, study period March 2020 - April 2020. risk of death, 5.9% higher, RR 1.06, p = 0.87, treatment 12 of 38 (31.6%), control 21 of 87 (24.1%), adjusted per study, inverted to make RR<1 favor treatment, odds ratio converted to relative risk, multivariable.
risk of mechanical ventilation, 49.8% lower, RR 0.50, p = 0.16, treatment 5 of 38 (13.2%), control 21 of 87 (24.1%), NNT 9.1, adjusted per study, odds ratio converted to relative risk, multivariable.
risk of ICU admission, 49.2% lower, RR 0.51, p = 0.41, treatment 9 of 38 (23.7%), control 38 of 87 (43.7%), NNT 5.0, adjusted per study, odds ratio converted to relative risk, multivariable.
Holt, 5/7/2020, retrospective, Denmark, peer-reviewed, median age 70.0, 4 authors, study period 1 March, 2020 - 1 April, 2020, excluded in exclusion analyses: unadjusted results with no group details. risk of death/ICU, 34.0% higher, RR 1.34, p = 0.09, treatment 35 of 116 (30.2%), control 129 of 573 (22.5%).
Kim (B), 9/4/2021, retrospective, propensity score matching, South Korea, peer-reviewed, 7 authors. risk of death, 700.0% higher, RR 8.00, p = 0.03, treatment 6 of 15 (40.0%), control 1 of 20 (5.0%), PSM, prior aspirin use.
risk of mechanical ventilation, 433.3% higher, RR 5.33, p = 0.14, treatment 4 of 15 (26.7%), control 1 of 20 (5.0%), PSM, prior aspirin use.
risk of ICU admission, 433.3% higher, RR 5.33, p = 0.14, treatment 4 of 15 (26.7%), control 1 of 20 (5.0%), PSM, prior aspirin use.
risk of case, 33.4% lower, RR 0.67, p = 0.29, treatment 15 of 136 (11.0%), control 20 of 136 (14.7%), NNT 27, adjusted per study, odds ratio converted to relative risk, PSM, logistic regression, prior aspirin use.
risk of death, 33.7% lower, RR 0.66, p = 0.22, treatment 14 of 124 (11.3%), control 23 of 135 (17.0%), NNT 17, PSM, aspirin treatment after diagnosis.
risk of mechanical ventilation, 102.2% higher, RR 2.02, p = 0.16, treatment 13 of 124 (10.5%), control 7 of 135 (5.2%), PSM, aspirin treatment after diagnosis.
risk of ICU admission, 90.5% higher, RR 1.91, p = 0.36, treatment 7 of 124 (5.6%), control 4 of 135 (3.0%), PSM, aspirin treatment after diagnosis.
Kurnik, 2/11/2025, retrospective, Slovenia, peer-reviewed, mean age 76.8, 3 authors, study period October 2020 - April 2021, excluded in exclusion analyses: unadjusted results with no group details. risk of death, 10.8% higher, RR 1.11, p = 0.37, treatment 33 of 40 (82.5%), control 67 of 90 (74.4%), day 1000.
Lal, 5/5/2022, retrospective, USA, peer-reviewed, 20 authors, study period 15 February, 2020 - 30 September, 2021, trial NCT04323787 (history). risk of death, 11.0% lower, HR 0.89, p = 0.01, treatment 4,691, control 16,888, adjusted per study, multivariable.
risk of ICU admission, 22.0% lower, HR 0.78, p < 0.001, treatment 4,691, control 16,888, adjusted per study, multivariable.
risk of progression, 9.0% lower, HR 0.91, p = 0.02, treatment 4,691, control 16,888, adjusted per study, multivariable.
Levy, 1/31/2022, retrospective, Israel, peer-reviewed, 10 authors. risk of death/hospitalization, 26.0% lower, HR 0.74, p = 0.13, treatment 29 of 159 (18.2%), control 178 of 690 (25.8%), NNT 13, adjusted per study, multivariable, Cox proportional hazards, day 40.
Lodigiani, 7/31/2020, retrospective, Italy, peer-reviewed, median age 66.0, 12 authors, study period 13 February, 2020 - 10 April, 2020. risk of ICU admission, 20.8% higher, RR 1.21, p = 0.52, treatment 17 of 94 (18.1%), control 44 of 294 (15.0%).
Loucera, 8/16/2022, retrospective, Spain, peer-reviewed, 8 authors, study period January 2020 - November 2020. risk of death, 17.7% lower, HR 0.82, p < 0.001, treatment 2,127, control 13,841, Cox proportional hazards, day 30.
Ma (B), 8/18/2021, retrospective, propensity score matching, United Kingdom, peer-reviewed, 9 authors. risk of death, 9.0% lower, OR 0.91, p = 0.12, treatment 12,471, control 64,750, RR approximated with OR.
risk of hospitalization, 2.0% lower, OR 0.98, p = 0.47, treatment 12,471, control 64,750, RR approximated with OR.
risk of symptomatic case, 9.0% higher, OR 1.09, p = 0.18, treatment 12,471, control 64,750, RR approximated with OR.
risk of case, 7.0% higher, OR 1.07, p = 0.09, treatment 12,471, control 64,750, RR approximated with OR.
Malik, 7/11/2022, retrospective, USA, peer-reviewed, 16 authors, study period 1 March, 2020 - 1 December, 2020. risk of death, 13.6% lower, RR 0.86, p = 0.72, treatment 15 of 87 (17.2%), control 24 of 223 (10.8%), adjusted per study, odds ratio converted to relative risk, multivariable.
risk of ICU admission, 27.8% lower, RR 0.72, p = 0.17, treatment 28 of 87 (32.2%), control 77 of 223 (34.5%), adjusted per study, odds ratio converted to relative risk, multivariable.
risk of ARDS, 25.1% lower, RR 0.75, p = 0.39, treatment 13 of 87 (14.9%), control 40 of 223 (17.9%), NNT 33, adjusted per study, odds ratio converted to relative risk, multivariable.
risk of hospitalization, 2.4% lower, OR 0.98, p = 0.94, treatment 25, control 176, adjusted per study, multivariable, RR approximated with OR.
Merzon, 2/23/2021, retrospective, Israel, peer-reviewed, 8 authors. risk of case, 27.6% lower, RR 0.72, p = 0.04, treatment 73 of 1,621 (4.5%), control 589 of 8,856 (6.7%), NNT 47, adjusted per study, odds ratio converted to relative risk.
risk of death, 62.4% lower, RR 0.38, p = 0.51, treatment 1 of 21 (4.8%), control 6 of 91 (6.6%), adjusted per study, odds ratio converted to relative risk.
time to viral-, 9.6% lower, relative time 0.90, p = 0.045, treatment 73, control 589, time to 2nd negative test.
time to viral-, 14.8% lower, relative time 0.85, p = 0.005, treatment 73, control 589, time to 1st negative test.
Miele, 12/8/2024, retrospective, USA, preprint, 12 authors, study period 1 January, 2020 - 31 March, 2021, excluded in exclusion analyses: substantial unadjusted confounding by indication possible. risk of death, 32.0% higher, OR 1.32, p = 0.02, RR approximated with OR.
Monserrat Villatoro, 1/8/2022, retrospective, propensity score matching, Spain, peer-reviewed, 18 authors. risk of death, 31.0% higher, OR 1.31, p = 0.04, RR approximated with OR.
Morrison, 10/10/2022, retrospective, USA, peer-reviewed, mean age 62.5, 3 authors, study period March 2020 - March 2021. risk of death, 7.7% lower, OR 0.92, p = 0.52, treatment 1,667, control 1,667, propensity score matching, RR approximated with OR.
risk of mechanical ventilation, 0.9% higher, OR 1.01, p = 0.96, treatment 1,667, control 1,667, propensity score matching, RR approximated with OR.
risk of ICU admission, 12.2% higher, OR 1.12, p = 0.36, treatment 1,667, control 1,667, propensity score matching, RR approximated with OR.
risk of hospitalization, 18.3% higher, OR 1.18, p = 0.04, treatment 1,667, control 1,667, propensity score matching, RR approximated with OR.
Mulhem, 4/7/2021, retrospective, database analysis, USA, peer-reviewed, 3 authors, excluded in exclusion analyses: substantial unadjusted confounding by indication likely; substantial confounding by time likely due to declining usage over the early stages of the pandemic when overall treatment protocols improved dramatically. risk of death, 13.9% higher, RR 1.14, p = 0.21, treatment 300 of 1,354 (22.2%), control 216 of 1,865 (11.6%), adjusted per study, odds ratio converted to relative risk, Table S1, logistic regression.
Nimer, 2/28/2022, retrospective, Jordan, peer-reviewed, survey, 4 authors, study period March 2021 - July 2021. risk of hospitalization, 3.7% lower, RR 0.96, p = 0.08, treatment 83 of 427 (19.4%), control 136 of 1,721 (7.9%), adjusted per study, odds ratio converted to relative risk, multivariable.
risk of severe case, 17.8% higher, RR 1.18, p = 0.28, treatment 98 of 427 (23.0%), control 162 of 1,721 (9.4%), adjusted per study, odds ratio converted to relative risk, multivariable.
Oh, 6/17/2021, retrospective, database analysis, South Korea, peer-reviewed, 4 authors. risk of death, 1.0% lower, OR 0.99, p = 0.95, adjusted per study, multivariable, RR approximated with OR.
risk of case, 12.0% lower, RR 0.88, p = 0.04, adjusted per study, odds ratio converted to relative risk, multivariable, control prevalance approximated with overall prevalence.
Osborne, 2/11/2021, retrospective, propensity score matching, USA, peer-reviewed, 6 authors. risk of death, 59.4% lower, RR 0.41, p < 0.001, treatment 272 of 6,300 (4.3%), control 661 of 6,300 (10.5%), NNT 16, odds ratio converted to relative risk, 30 days, PSM.
risk of death, 60.5% lower, RR 0.40, p < 0.001, treatment 170 of 6,814 (2.5%), control 427 of 6,814 (6.3%), NNT 27, odds ratio converted to relative risk, 14 days, PSM.
Pan, 5/26/2021, retrospective, USA, peer-reviewed, 11 authors, study period 1 March, 2020 - 9 April, 2020. risk of death, 13.0% higher, OR 1.13, p = 0.63, treatment 239, control 523, adjusted per study, MOS 6 vs. <6, multivariable, RR approximated with OR.
risk of death/intubation, 2.0% higher, OR 1.02, p = 0.93, treatment 239, control 523, adjusted per study, MOS 5+ vs. <5, multivariable, RR approximated with OR.
Prieto-Campo, 1/6/2024, retrospective, Spain, peer-reviewed, 6 authors. risk of death, 13.0% higher, OR 1.13, p = 0.38, adjusted per study, case control OR.
risk of hospitalization, 3.0% lower, OR 0.97, p = 0.64, adjusted per study, case control OR.
risk of progression, no change, OR 1.00, p = 0.98, adjusted per study, case control OR.
risk of case, 8.0% lower, OR 0.92, p = 0.02, adjusted per study, case control OR.
Pérez-Segura, 10/4/2021, retrospective, multiple countries, peer-reviewed, 23 authors. risk of death, 49.1% higher, RR 1.49, p < 0.001, treatment 66 of 155 (42.6%), control 183 of 608 (30.1%), odds ratio converted to relative risk.
Ramos-Rincón, 12/28/2020, retrospective, Spain, preprint, 25 authors, study period 1 March, 2020 - 29 May, 2020. risk of death, 28.9% higher, RR 1.29, p = 0.02, treatment 132 of 264 (50.0%), control 253 of 526 (48.1%), adjusted per study, odds ratio converted to relative risk, multivariable.
Reese, 4/20/2021, retrospective, USA, preprint, 23 authors. risk of death, 61.0% higher, HR 1.61, p < 0.001, treatment 4,921, control 4,921, propensity score matching, Cox proportional hazards, Table S55.
risk of severe case, 309.0% higher, OR 4.09, p < 0.001, treatment 4,921, control 4,921, propensity score matching, Table S47, RR approximated with OR.
Sakamaki, 9/27/2024, retrospective, Japan, peer-reviewed, mean age 52.1, 3 authors, study period 15 January, 2020 - 31 December, 2022. risk of severe case, 37.0% higher, OR 1.37, p < 0.001, adjusted per study, multivariable, RR approximated with OR.
Sisinni, 10/4/2021, retrospective, Italy, peer-reviewed, 18 authors. risk of death, 7.1% higher, RR 1.07, p = 0.65, treatment 93 of 253 (36.8%), control 251 of 731 (34.3%).
risk of death or respiratory support upgrade, 30.3% lower, RR 0.70, p = 0.01, treatment 253, control 731, multivariate.
Son, 7/30/2021, retrospective, propensity score matching, South Korea, peer-reviewed, 6 authors. risk of death, 11.0% lower, OR 0.89, p = 0.67, treatment 58 of 210 (27.6%) cases, 54 of 210 (25.7%) controls, adjusted per study, case control OR, group 2, model 1, multivariable.
risk of death, 24.0% lower, OR 0.76, p = 0.52, treatment 37 of 128 (28.9%) cases, 31 of 128 (24.2%) controls, adjusted per study, case control OR, group 1, model 2, multivariable.
risk of progression, 7.0% higher, OR 1.07, p = 0.80, treatment 77 of 339 (22.7%) cases, 58 of 339 (17.1%) controls, adjusted per study, case control OR, complications, group 1, model 2, multivariable.
risk of progression, 9.0% lower, OR 0.91, p = 0.61, treatment 77 of 339 (22.7%) cases, 58 of 339 (17.1%) controls, adjusted per study, case control OR, complications, group 2, model 1, multivariable.
risk of case, 11.0% higher, OR 1.11, p = 0.21, treatment 313 of 3,825 (8.2%) cases, 531 of 7,650 (6.9%) controls, adjusted per study, case control OR, group 1, PSM 1, model 2, multivariable.
risk of case, 1.0% higher, OR 1.01, p = 0.90, treatment 431 of 7,223 (6.0%) cases, 752 of 14,446 (5.2%) controls, adjusted per study, case control OR, group 2, PSM 1, model 1, multivariable.
Sullerot, 1/7/2022, retrospective, propensity score weighting, multiple countries, peer-reviewed, 15 authors, study period 1 March, 2020 - 31 December, 2020. risk of death, 10.0% higher, RR 1.10, p = 0.52, treatment 101 of 301 (33.6%), control 224 of 746 (30.0%).
risk of ICU admission, 109.7% higher, RR 2.10, p = 0.007, treatment 22 of 301 (7.3%), control 26 of 746 (3.5%).
hospitalization time, 10.0% higher, relative time 1.10, p = 0.02, treatment 301, control 746.
Tse, 6/2/2023, retrospective, China, peer-reviewed, 12 authors, study period 1 January, 2020 - 8 December, 2020. risk of death/intubation, 67.0% lower, OR 0.33, p < 0.001, adjusted per study, propensity score matching, multivariable, day 30, RR approximated with OR.
Wang (B), 7/14/2020, retrospective, USA, peer-reviewed, 13 authors. risk of death, 57.7% lower, RR 0.42, p = 0.43, treatment 1 of 9 (11.1%), control 13 of 49 (26.5%), NNT 6.5, odds ratio converted to relative risk.
Ware, 4/12/2024, retrospective, propensity score matching, USA, preprint, 7 authors, study period 2 March, 2020 - 13 June, 2022. risk of death, 45.8% lower, RR 0.54, p = 0.001, treatment 7,531 of 81,830 (9.2%), control 13,890 of 81,830 (17.0%), NNT 13, propensity score matching, day 365.
Yuan, 12/18/2020, retrospective, China, peer-reviewed, 6 authors. risk of death, 4.4% lower, RR 0.96, p = 0.89, treatment 11 of 52 (21.2%), control 29 of 131 (22.1%), NNT 102, odds ratio converted to relative risk, mutivariate.
Zadeh, 12/20/2022, retrospective, USA, peer-reviewed, mean age 62.2, 8 authors. risk of death, 37.0% lower, RR 0.63, p = 0.28.
risk of ICU admission, 1.0% higher, RR 1.01, p = 0.79.
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.
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 environment249,250. Research also suggests potential cardioprotective effects at lower doses, but cardiotoxicity with excessive dosage251. 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.