Azithromycin for COVID-19: real-time meta-analysis of 31 studies

Meta-analysis31 studies · 50K patientsc19early.org

Azithromycin for COVID-19

Serious outcome risk
Azithromycin
Control
Outcome (studies)
Improvement
Relative risk · 95% CI
All studies (31)11%
Mortality (24)11%
Ventilation (6)8%
ICU admission (4)16%
Progression (3)19%
Recovery (4)5%
Cases (2)19%
RCTs (11)4%
Peer-reviewed (30)13%
Prophylaxis (4)14%
Early (3)26%
Late (24)9%
after exclusions
00.511.5+
← Azithromycin
reduces risk
Increased
risk →
Abstract
Meta-analysis using the most serious outcome reported shows 11% [0‑21%] lower risk. Results are similar for higher quality and peer-reviewed studies and worse for Randomized Controlled Trials. Early treatment is more effective than late treatment.
10 studies from 10 independent teams in 8 countries show significant benefit.
In worst case exclusion sensitivity analysis, statistical significance is lost after excluding 2 of 31 studies.
Meta-analysis31 studies · 50K patientsc19early.org

Azithromycin for COVID-19

Serious outcome risk
Azithromycin
Control
Outcome (studies)
Improvement
Relative risk · 95% CI
All studies (31)11%
Mortality (24)11%
Ventilation (6)8%
ICU admission (4)16%
Progression (3)19%
Recovery (4)5%
Cases (2)19%
RCTs (11)4%
Peer-reviewed (30)13%
Prophylaxis (4)14%
Early (3)26%
Late (24)9%
after exclusions
00.511.5+
← Azithromycin
reduces risk
Increased
risk →
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.
Evolution of COVID-19 clinical evidence Meta-analysis results over time Azithromycin p=0.044 Acetaminophen p=0.00000021 2020 2021 2022 2023 2024 2025 2026 Lowerrisk Higherrisk c19early.org October 2026 50% 0% -50%

Azithromycin for COVID-19

Highlights
  • Azithromycin reduces risk with high confidence for pooled analysis, low confidence for mortality, and very low confidence for cases.
  • Early treatment is more effective than late treatment.
  • Real-time updates and corrections with a consistent protocol for 227 treatments. Outcome specific analysis and combined evidence from all studies including treatment delay, a primary confounding factor.
A
October 2026

Azithromycin COVID-19 studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment26%0.74 · 0.63–0.8641/25949/25126% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.00015
Late treatment9%0.91 · 0.77–1.081,410/15,6061,482/16,3329% lower risk
Tau² = 0.08, I² = 86.4%, p = 0.28
Prophylaxis14%0.86 · 0.77–0.973/2,471875/16,30214% lower risk
Tau² = 0.01, I² = 49.2%, p = 0.017
All studies11%0.89 · 0.79–1.001,454/18,3362,406/32,88511% lower risk
Tau² = 0.05, I² = 85.8%, p = 0.04400.511.52+
1 CT: study uses combined treatment
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← Azithromycin
reduces risk
Azithromycin
increases risk →
B
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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 azithromycin studies.
Fig. 2. SARS-CoV-2 spike protein fibrin binding leads to thromboinflammation and neuropathology, from1.
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 injury2-18 and cognitive deficits5,10, cardiovascular complications19-25, DNA damage26-29, organ failure, and death. Even mild untreated infections may result in persistent cognitive deficits30—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,31-38, providing many therapeutic targets for which many existing compounds have known activity. Scientists have predicted that over 12,000 compounds may reduce COVID-19 risk39, either by directly minimizing infection or replication, by supporting immune system function, or by minimizing secondary complications.
We analyze all significant controlled studies of azithromycin 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.
3 in silico studies support the efficacy of azithromycin47-49.
2 in vitro studies support the efficacy of azithromycin50,51.
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, with different 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, 14, and 15 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, peer reviewed studies, and transmission.
Table 1. Random-effects meta-analysis for all stages combined, for Randomized Controlled Trials, for peer-reviewed studies, with different exclusions, and for specific outcomes. Results show the relative risk with treatment and the 95% confidence interval. * p<0.05  *** p<0.001.
Relative Risk Studies Patients
All studies0.89 [0.79‑1.00]*3150K
After exclusions0.82 [0.73‑0.93]**2630K
Peer-reviewedPeer-reviewed0.87 [0.78‑0.98]*3040K
RCTsRCTs0.96 [0.89‑1.04]1110K
RCTs after exclusionsRCTs w/exc.0.76 [0.58‑1.01]93,081
Mortality0.89 [0.77‑1.03]2440K
VentilationVent.0.92 [0.77‑1.10]69,393
ICU admissionICU0.84 [0.53‑1.33]41,750
HospitalizationHosp.0.84 [0.62‑1.13]41,741
Recovery0.95 [0.85‑1.05]42,011
Cases0.81 [0.57‑1.13]20
Viral0.83 [0.53‑1.29]2510
RCT mortality0.98 [0.90‑1.06]79,413
RCT hospitalizationRCT hosp.0.84 [0.62‑1.13]41,741
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.
Early treatment Late treatment Prophylaxis
All studies0.74 [0.63‑0.86]***0.74***
[0.63‑0.86]
0.91 [0.77‑1.08]0.91
[0.77‑1.08]
0.86 [0.77‑0.97]*0.86*
[0.77‑0.97]
After exclusions0.74 [0.63‑0.86]***0.74***
[0.63‑0.86]
0.81 [0.66‑0.99]*0.81*
[0.66‑0.99]
0.86 [0.77‑0.97]*0.86*
[0.77‑0.97]
Peer-reviewedPeer-reviewed0.74 [0.63‑0.86]***0.74***
[0.63‑0.86]
0.89 [0.75‑1.05]0.89
[0.75‑1.05]
0.86 [0.77‑0.97]*0.86*
[0.77‑0.97]
RCTsRCTs0.77 [0.55‑1.06]0.77
[0.55‑1.06]
0.98 [0.90‑1.06]0.98
[0.90‑1.06]
RCTs after exclusionsRCTs w/exc.0.77 [0.55‑1.06]0.77
[0.55‑1.06]
0.76 [0.43‑1.32]0.76
[0.43‑1.32]
Mortality0.91 [0.77‑1.08]0.91
[0.77‑1.08]
0.66 [0.34‑1.28]0.66
[0.34‑1.28]
VentilationVent.0.92 [0.77‑1.10]0.92
[0.77‑1.10]
ICU admissionICU0.84 [0.53‑1.33]0.84
[0.53‑1.33]
HospitalizationHosp.1.33 [0.30‑5.86]1.33
[0.30‑5.86]
0.85 [0.56‑1.29]0.85
[0.56‑1.29]
Recovery2.00 [0.51‑7.85]2.00
[0.51‑7.85]
0.94 [0.85‑1.05]0.94
[0.85‑1.05]
Cases0.81 [0.57‑1.13]0.81
[0.57‑1.13]
Viral0.83 [0.53‑1.29]0.83
[0.53‑1.29]
RCT mortality0.98 [0.90‑1.06]0.98
[0.90‑1.06]
RCT hospitalizationRCT hosp.1.33 [0.30‑5.86]1.33
[0.30‑5.86]
0.85 [0.56‑1.29]0.85
[0.56‑1.29]
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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

Azithromycin COVID-19 studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment26%0.74 · 0.63–0.8641/25949/25126% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.00015
Late treatment9%0.91 · 0.77–1.081,410/15,6061,482/16,3329% lower risk
Tau² = 0.08, I² = 86.4%, p = 0.28
Prophylaxis14%0.86 · 0.77–0.973/2,471875/16,30214% lower risk
Tau² = 0.01, I² = 49.2%, p = 0.017
All studies11%0.89 · 0.79–1.001,454/18,3362,406/32,88511% lower risk
Tau² = 0.05, I² = 85.8%, p = 0.04400.511.52+
1 CT: study uses combined treatment
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← Azithromycin
reduces risk
Azithromycin
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

Azithromycin COVID-19 mortality results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment9%0.91 · 0.77–1.081,403/14,9851,477/15,6359% lower risk
Tau² = 0.08, I² = 87.4%, p = 0.27
Prophylaxis34%0.66 · 0.34–1.282,465 (n)13,503 (n)34% lower risk
Tau² = 0.17, I² = 70.2%, p = 0.22
All studies11%0.89 · 0.77–1.031,403/17,4501,477/29,13811% lower risk
Tau² = 0.07, I² = 86.9%, p = 0.1200.511.52+
1 CT: study uses combined treatment
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increases risk →
Fig. 6. Random-effects meta-analysis for mortality results.
October 2026

Azithromycin COVID-19 mechanical ventilation results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment8%0.92 · 0.77–1.10235/3,499484/5,8948% lower risk
Tau² = 0.00, I² = 1.8%, p = 0.37
All studies8%0.92 · 0.77–1.10235/3,499484/5,8948% lower risk
Tau² = 0.00, I² = 1.8%, p = 0.3700.511.52+
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Fig. 7. Random-effects meta-analysis for ventilation.
October 2026

Azithromycin COVID-19 ICU results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment16%0.84 · 0.53–1.3316/89619/85416% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.46
All studies16%0.84 · 0.53–1.3316/89619/85416% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.4600.511.52+
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Fig. 8. Random-effects meta-analysis for ICU admission.
October 2026

Azithromycin COVID-19 hospitalization results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment−33%1.33 · 0.30–5.864/1523/15233% higher risk
Tau² = 0.00, I² = 0.0%, p = 0.72
Late treatment15%0.85 · 0.56–1.2921/68122/75615% lower risk
Tau² = 0.05, I² = 32.1%, p = 0.46
All studies16%0.84 · 0.62–1.1325/83325/90816% lower risk
Tau² = 0.02, I² = 11.8%, p = 0.2500.511.52+
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← Azithromycin
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increases risk →
Fig. 9. Random-effects meta-analysis for hospitalization.
October 2026

Azithromycin COVID-19 progression results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Early treatment67%0.33 · 0.04–3.171/1523/15267% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.34
Late treatment80%0.20 · 0.01–4.050/1192/11480% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.3
Prophylaxis−54%1.54 · 0.69–3.423/6875/2,79954% higher risk
Tau² = 0.00, I² = 0.0%, p = 0.3
All studies19%0.81 · 0.23–2.834/277880/3,06519% lower risk
Tau² = 0.47, I² = 32.7%, p = 0.7600.511.52+
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Fig. 10. Random-effects meta-analysis for progression.
October 2026

Azithromycin COVID-19 recovery results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment−100%2.00 · 0.51–7.856/1523/152100% higher risk
Tau² = 0.00, I² = 0.0%, p = 0.33
Late treatment6%0.94 · 0.85–1.0565/75035/9576% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.27
All studies5%0.95 · 0.85–1.0571/90238/1,1095% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.3100.511.52+
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Fig. 11. Random-effects meta-analysis for recovery.
October 2026

Azithromycin COVID-19 case results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Prophylaxis19%0.81 · 0.57–1.1319% lower risk
Tau² = 0.04, I² = 42.1%, p = 0.21
All studies19%0.81 · 0.57–1.1319% lower risk
Tau² = 0.04, I² = 42.1%, p = 0.2100.511.52+
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Fig. 12. Random-effects meta-analysis for cases.
October 2026

Azithromycin COVID-19 viral clearance results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment17%0.83 · 0.53–1.29259 (n)251 (n)17% lower risk
Tau² = 0.10, I² = 94.9%, p = 0.41
All studies17%0.83 · 0.53–1.29259 (n)251 (n)17% lower risk
Tau² = 0.10, I² = 94.9%, p = 0.4100.511.52+
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Azithromycin
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Fig. 13. Random-effects meta-analysis for viral clearance.
October 2026

Azithromycin COVID-19 peer reviewed studies

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment26%0.74 · 0.63–0.8641/25949/25126% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.00015
Late treatment11%0.89 · 0.75–1.051,410/13,5921,482/14,87311% lower risk
Tau² = 0.08, I² = 85.0%, p = 0.18
Prophylaxis14%0.86 · 0.77–0.973/2,471875/16,30214% lower risk
Tau² = 0.01, I² = 49.2%, p = 0.017
All studies13%0.87 · 0.78–0.981,454/16,3222,406/31,42613% lower risk
Tau² = 0.04, I² = 84.8%, p = 0.0200.511.52+
1 CT: study uses combined treatment
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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.
October 2026

Azithromycin COVID-19 transmission results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Late treatment12%0.88 · 0.51–1.5033/52220/27812% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.65
All studies12%0.88 · 0.51–1.5033/52220/27812% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.6500.511.52+
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← Azithromycin
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Azithromycin
increases risk →
Fig. 15. Random-effects meta-analysis for transmission. 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. 16 shows a comparison of results for RCTs and observational studies. Fig. 17, 18, 19, 20, and 21 show forest plots for random-effects meta-analysis of all Randomized Controlled Trials, RCTs after exclusions, RCT mortality results, RCT mortality results after exclusions, and RCT hospitalization results. RCT results are included in Table 1 and Table 2.
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Fig. 16. 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 biases54, and analysis of double-blind RCTs has identified extreme levels of bias55. 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 azithromycin 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. 22. For COVID-19, observational study results do not systematically differ from RCTs, RR 0.97 [0.91‑1.03] across 227 treatments59.
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]44. 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 see63,64.
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

Azithromycin COVID-19 Randomized Controlled Trials

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment23%0.77 · 0.55–1.0641/25949/25123% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.11
Late treatment2%0.98 · 0.90–1.06674/4,1351,255/6,5962% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.6
All studies4%0.96 · 0.89–1.04715/4,3941,304/6,8474% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.3600.511.52+
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← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 17. 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

Azithromycin COVID-19 Randomized Controlled Trials after exclusions

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment23%0.77 · 0.55–1.0641/25949/25123% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.11
Late treatment24%0.76 · 0.43–1.3223/1,33920/1,23224% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.33
All studies24%0.76 · 0.58–1.0164/1,59869/1,48324% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.0600.511.52+
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← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 18. Random-effects meta-analysis for RCTs after exclusions. 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.
October 2026

Azithromycin COVID-19 RCT mortality results

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment2%0.98 · 0.90–1.06667/3,5141,250/5,8992% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.6
All studies2%0.98 · 0.90–1.06667/3,5141,250/5,8992% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.600.511.52+
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← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 19. Random-effects meta-analysis for RCT mortality results.
October 2026

Azithromycin COVID-19 RCT mortality results after exclusions

StudyImprovementRR · 95% CITreatmentControlRelative Risk
Late treatment28%0.72 · 0.39–1.3116/71815/53528% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.28
All studies28%0.72 · 0.39–1.3116/71815/53528% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.2800.511.52+
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← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 20. Random-effects meta-analysis for RCT mortality results after exclusions.
October 2026

Azithromycin COVID-19 RCT hospitalization results

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment−33%1.33 · 0.30–5.864/1523/15233% higher risk
Tau² = 0.00, I² = 0.0%, p = 0.72
Late treatment15%0.85 · 0.56–1.2921/68122/75615% lower risk
Tau² = 0.05, I² = 32.1%, p = 0.46
All studies16%0.84 · 0.62–1.1325/83325/90816% lower risk
Tau² = 0.02, I² = 11.8%, p = 0.2500.511.52+
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← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 21. Random-effects meta-analysis for RCT hospitalization results.
To avoid bias in the selection of studies, we analyze all non-retracted studies. Here we show the results after excluding studies with major issues likely to alter results, non-standard studies, and studies where very minimal detail is currently available. Our bias evaluation is based on analysis of each study and identifying when there is a significant chance that limitations will substantially change the outcome of the study. We believe this can be more valuable than checklist-based approaches such as Cochrane GRADE, which can be easily influenced by potential bias, may ignore or underemphasize serious issues not captured in the checklists, and may overemphasize issues unlikely to alter outcomes in specific cases (for example certain specifics of randomization with a very large effect size and well-matched baseline characteristics).
The studies excluded are as below. Fig. 23 shows a forest plot for random-effects meta-analysis of all studies after exclusions.
Frontera, substantial confounding by time likely due to declining usage over the early stages of the pandemic when overall treatment protocols improved dramatically.
Furtado, very late stage patients.
Gadhiya, substantial unadjusted confounding by indication likely.
Horby, very late stage patients.
Kuderer, substantial unadjusted confounding by indication likely.
October 2026

Azithromycin COVID-19 studies after exclusions

StudyImprovementRR · 95% CIOutcomeTreatmentControlRelative Risk
Early treatment26%0.74 · 0.63–0.8641/25949/25126% lower risk
Tau² = 0.00, I² = 0.0%, p = 0.00015
Late treatment19%0.81 · 0.66–0.99704/10,521194/8,92219% lower risk
Tau² = 0.08, I² = 76.1%, p = 0.04
Prophylaxis14%0.86 · 0.77–0.973/2,471875/16,30214% lower risk
Tau² = 0.01, I² = 49.2%, p = 0.017
All studies18%0.82 · 0.73–0.93748/13,2511,118/25,47518% lower risk
Tau² = 0.04, I² = 81.5%, p = 0.001800.511.52+
1 CT: study uses combined treatment
Rotate screen for more detailsIncrease width for more details
← Azithromycin
reduces risk
Azithromycin
increases risk →
Fig. 23. 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."40.
We analyze media coverage for the 227 treatments we cover using Altmetric70 and PlumX Metrics71. Altmetric covers ~14,000 news outlets72 and PlumX covers ~55,000 news sources73. The two services are complementary with coverage of different news sources and different methods for identifying articles not containing a DOI. We consider studies to have received significant media coverage if they were covered by at least 100 articles in either Altmetric of PlumX73,74. The most widespread study was covered by 1,047 outlets. Studies covered by major syndicated sources shows hundreds of news articles, while studies covered by few outlets typically appear in niche medical news sources or press releases. Fig. 24 and 25 show bias towards negative results for low-cost treatments, in contrast to the opposite bias for high-profit treatments.
The media bias may result in widespread incorrect perceptions on the relative efficacy of high-profit and low-cost treatments. The impact is significant—increased cost limits the use of high-profit treatments and treatment equity. High-profit treatments were also more difficult to access, especially for earlier treatment which improves efficacy and minimizes community transmission.
October 2026

Media coverage of low-cost COVID‑19 treatments

Media covered only 0.8% of studies showing significantly lower COVID-19 risk

Only 5 positive studies were covered

0.8%

34 negative studies were covered

4%
5.4×
Negative bias for low-cost treatments
negative studies were 5.4 times more likely to be covered
Fig. 24. Mainstream media coverage was biased against positive results for low-cost treatments. When restricting to RCTs, the bias was even larger, with negative RCTs 6.9× more likely to be covered.
October 2026

Media coverage of high-profit COVID‑19 treatments

Media was 3.8× more likely to cover positive studies

19 positive studies were covered

11%

Only 6 negative studies were covered

3%
3.8×
Positive bias for high-profit treatments
positive studies were 3.8 times more likely to be covered
Fig. 25. For high-profit treatments, mainstream media coverage was biased towards positive results. When restricting to RCTs, the bias was even larger, with positive RCTs 12.0× more likely to be covered.
A combination of factors may have led to the very low media coverage of low-cost treatments:
•
Politicization
led to a media environment where coverage was often framed to support a political narrative rather than to provide objective scientific information. As Scott Alexander said:
"if you say anything in favor of ivermectin you will be cast out of civilization and thrown into the circle of social hell reserved for Klan members and 1/6 insurrectionists. All the health officials in the world will shout 'horse dewormer!' at you and compare you to Josef Mengele."
There was strong social pressure to discredit low-cost treatments.
•
Censorship
of information conflicting with selected authorities. For example, individuals and organizations presenting conflicting science were often shadowbanned or completely banned on Twitter and YouTube if the science they were reporting conflicted with the opinions of specific authorities selected by those companies, including when the authorities had not even reviewed the scientific results in question.
•
FDA requires "no adequate, approved, and available alternatives"
in order to grant an EUA for novel high-profit interventions, creating an incentive for authorities to ignore or downplay existing low-cost treatments.
•
Regulatory capture
biases authorities towards high-profit interventions.
•
Authorities ignored most evidence for low-cost treatments
, for example the NIH references only 2% of studies in delayed, rarely-updated, biased commentaries with no quantitive analysis.
•
Media coverage of science is often not very accurate
, e.g., misunderstanding confounding issues. For example the media widely considered the RECOVERY HCQ RCT to be conclusive on efficacy, but very late treatment of late-stage patients (mostly on oxygen already) with an excessive toxic dose (shown dangerous in a dose comparison RCT) provides no information on the recommended early/prophylactic treatment. With difficulting in understanding basic confounders like treatment delay and dose, the media may favor deferring to authorities. Many studies for low-cost treatments require greater expertise to analyze.
•
Substantial funding from pharmaceutical advertising
biases editorial decisions towards high-profit interventions.
•
PR power
- companies/teams with strong PR presence are favored in the media, which correlates with high-profit and high conflict of interest studies.
•
The media was very negative in general
, inflating risk, and elevating fear and anxiety. A negative bias may improve ratings and revenue, increasing motivation to continue watching coverage.
26 low-cost treatments were approved in one or more countries, yet many countries approved no low-cost treatments. The countries that did adopt low-cost treatments analyzed the evidence early and made timely approvals. With few exceptions, authorities did not change their initial views, regardless of how much evidence accumulated showing either efficacy or harm. Why?
The harms of smoking here hidden for 25 yearsC. Authorities did not analyze the data in real-time, failing to act when harm was known. Widespread acknowledgement of harm came only after attempts by two new surgeon generals, along with pressure from health advocates and a new president, and a review of 7,000 studies.
Similarly for COVID-19, most authorities and experts did not proactively analyze data in real-time. This guarantees delayed recognition of efficacy or harm, by which time moral, legal, career, and reputational liabilities strongly disincentivize any admission of error. Claims of no efficacy (for effective treatments) or safety (for harmful treatments) were often made prior to strong data being available. Correction would require admitting to errors that increased mortality, which is unlikely with the same generation of officials.
Analysis of potential treatments was rarely done, and when done these were typically minimal efforts. For example, NIH reviews were highly delayed, cover only a tiny fraction of treatments, reference only 2% of studies for the treatments covered, and include no quantitative analysis. They appear as rarely updated side projects from external panels implicitly tasked with justifying prior failures. As with smoking, the thousands of studies could (and should) have been analyzed and acted on in real-time.
A key structural improvement, applicable to all current and future diseases, is for authorities to implement real-time proactive analysis of clinical evidence. This does not remove all bias, but does make it possible to act on evidence, whereas delayed action may be unlikely due to moral, legal, career, and reputational liabilities.
c19early.org
Delayed public health acknowledgments
Official acknowledgment of efficacy or harm is often delayed—legal, career, and status risks disincentivize admission of error.
Evidence Official Acknowledgment Approx. Delay
Citrus Fruit (vitamin C) for Scurvy (effectiveness) 1747: James Lind conducted one of the first-ever controlled clinical trials, proving that oranges and lemons cured scurvy in sailors. 1795: The British Royal Navy finally made a daily ration of lemon juice a standard issue for all its sailors, effectively eliminating the disease. 48 years
Handwashing (lower mortality) 1847: Dr. Ignaz Semmelweis provided conclusive proof that having doctors wash their hands with a chlorine solution before delivering babies reduced maternal mortality rates from over 18% to around 1%. ~1870s: Semmelweis's findings were rejected and he was ridiculed. His work was only validated decades later (after his death). ~20+ years
Helicobacter pylori (bacteria causes ulcers) 1982-1984: Marshall and Warren discovered that Helicobacter pylori bacteria causes ulcers, confirmed via direct exposure. Officials maintained that ulcers were caused by stress and spicy food. 1994: The US NIH released a consensus statement officially recommending antibiotics as the standard treatment for peptic ulcers, overturning decades of acid-suppression therapy. ~12 years
Asbestos (causes asbestosis & cancer) 1924: The British Medical Journal published the first case study of a death from "asbestosis." By 1918, U.S. insurance companies had stopped selling life insurance to asbestos workers. 1971 (US): The Occupational Safety and Health Administration (OSHA) was formed and began regulating asbestos as a carcinogen, setting the first federal workplace safety standards for it. ~47 years
Leaded Gasoline (neurotoxicity) ~1924: Dangers of low-level lead exposure were known. Experts like Alice Hamilton warned the U.S. Surgeon General that adding lead to gasoline would cause widespread public poisoning. 1973 (US): The Environmental Protection Agency (EPA) ordered the first phasedown of lead in gasoline, following the Clean Air Act of 1970. A full ban for on-road vehicles took effect in 1996. ~49 years
Harms of Smoking (causes lung cancer) 1939: Franz Müller (Germany) published the first case-control epidemiological study strongly linking tobacco smoking to lung cancer. This was followed by major U.S. & U.K. studies in the 1950s. 1964 (US): The U.S. Surgeon General's report, "Smoking and Health," was released. It was the first U.S. government report to definitively link smoking to lung cancer and heart disease. 25 years
Heterogeneity in COVID-19 studies arises from many factors including:
The time between infection or the onset of symptoms and treatment may critically affect how well a treatment works. For example an antiviral may be very effective when used early but may not be effective in late stage disease, and may even be harmful. Oseltamivir, for example, is generally only considered effective for influenza when used within 0-36 or 0-48 hours75,76. 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 cases77
<24 hours-33 hours symptoms78
24-48 hours-13 hours symptoms78
Inpatients-2.5 hours to improvement79
Fig. 26 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. 26. 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 variants81, for example the Gamma variant shows significantly different characteristics82-85. 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 variants86,87.
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 synergistic90-114, 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. 27 shows that lower hospitalization is very strongly associated with lower mortality (p < 0.0000000001). Similarly, Fig. 28 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. 29 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. 27. Lower hospitalization is associated with lower mortality, supporting pooled outcome analysis.
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Fig. 28. Improved recovery is associated with lower mortality, supporting pooled outcome analysis.
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Fig. 27. 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. 30 shows when treatments were found effective during the pandemic. Pooled outcomes often resulted in earlier detection of efficacy.
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Fig. 30. 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 targets45. Studies show complementary and synergistic effects with polytherapy90-114. For example, Jitobaom et al.91 shows >10x reduction in IC50 with ivermectin and niclosamide, an RCT by Said et al.98 showed the combination of nigella sativa and vitamin D was more effective than either alone, and an RCT by Wannigama et al.116 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 pressure117-124. Antigenic drift can undermine more variant-specific treatments like monoclonal antibodies and more specific antivirals. Treatment with targeted antivirals may select for escape mutations125. The efficacy of treatments varies depending on cell type126 due to differences in viral receptor expression, drug distribution and metabolism, and cell-specific mechanisms. Efficacy may also vary based on genetic variants127-137.
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-analysis138. As with all treatments, azithromycin studies using polytherapy show greater efficacy than monotherapy studies. This comparison includes combined treatment studies excluded from the rest of this paper138.
Polytherapy vs. monotherapy for azithromycin
Monotherapy Polytherapy
Late treatment
7% [-11–21%]
66% [21–85%]
c19early.org
Combined treatment is more effective
SARS-CoV-2 involves the complex interplay of 500+ host and viral proteins and factors, providing many therapeutic targets. Many compounds have antiviral activity for SARS-CoV-2, with many different mechanisms including blocking attachment, entry, and replication. Combinations of treatments, with careful attention to potential side effects, allows improved efficacy via complementary and synergistic mechanisms.
Tissue and cell coverage Different compounds have different tissue penetration profiles and efficacy across cell types
Variant coverage Compounds with different viral resistance profiles
Intra/extracellular Disabling and removing intracellular and extracellular viral particles
Resistance Minimizing persistence and emergence of resistant variants
Genetics Robustness against individual variations in efficacy based on genetics
Lower doses Potentially lower doses of individual agents, reducing toxicity
Viral and host-directed Antivirals targeting viral and host proteins
Immune system function Supporting or enhancing natural immune system function
Disease phases Addressing multiple disease phases (viral replication, inflammation, secondary complications)
Publishing is often biased towards positive results, however evidence suggests that there may be a negative bias for inexpensive treatments for COVID-19. Both negative and positive results are very important for COVID-19, media in many countries prioritizes negative results for inexpensive treatments (inverting the typical incentive for scientists that value media recognition), and there are many reports of difficulty publishing positive results139-142.
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. 31 shows a scatter plot of results for prospective and retrospective studies. 40% of retrospective studies report a statistically significant positive effect for one or more outcomes, compared to 18% of prospective studies, consistent with a bias toward publishing positive results. The median effect size for retrospective studies is 10% improvement, compared to 3% for prospective studies, suggesting a potential bias towards publishing results showing higher efficacy.
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Fig. 31. 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. 32 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 < 0.05143-150. 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. 32. 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. Azithromycin for COVID-19 lacks this because it is off-patent, has multiple manufacturers, and is very low cost. In contrast, most COVID-19 azithromycin 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 azithromycin 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 alone90-114. Therefore standard of care may be critical and benefits may diminish or disappear if standard of care does not include certain treatments.
This real-time analysis is constantly updated based on submissions. Accuracy benefits from widespread review and submission of updates and corrections from reviewers. Less popular treatments may receive fewer reviews.
No treatment or intervention is 100% available and effective for all current and future variants. Efficacy may vary significantly with different variants and within different populations. All treatments have potential side effects. Propensity to experience side effects may be predicted in advance by qualified physicians. We do not provide medical advice. Before taking any medication, consult a qualified physician who can compare all options, provide personalized advice, and provide details of risks and benefits based on individual medical history and situations.
1 of 31 studies combine treatments. The results of azithromycin alone may differ. None of the RCTs use combined treatment.
Enyeji et al. present a review covering azithromycin for COVID-19.
Additional preclinical or review papers suggesting potential benefits of azithromycin for COVID-19 include178-212. 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 factors31-38, providing many therapeutic targets. Over 12,000 compounds have been predicted to reduce COVID-19 risk39, either by directly minimizing infection or replication, by supporting immune system function, or by minimizing secondary complications. Fig. 33 shows an overview of the results for azithromycin in the context of multiple COVID-19 treatments, and Fig. 34 shows a plot of efficacy vs. cost for COVID-19 treatments.
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Fig. 33. 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 efficacy213.
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Fig. 34. Efficacy vs. cost for COVID-19 treatments.
Meta-analysis using the most serious outcome reported shows 11% [0‑21%] lower risk. Results are similar for higher quality and peer-reviewed studies and worse for Randomized Controlled Trials. Early treatment is more effective than late treatment. 10 studies from 10 independent teams in 8 countries show significant benefit.
In worst case exclusion sensitivity analysis, statistical significance is lost after excluding 2 of 31 studies.
 
Contact.
Contact us on X at @CovidAnalysis.
Funding.
We have received no funding or compensation in any form, and do not accept donations. This is entirely volunteer work.
Conflicts of interest.
We have no conflicts of interest. We have no affiliation with any pharmaceutical companies, supplement companies, governments, political parties, or advocacy organizations.
AI.
We use AI models (Gemini, Grok, Claude, and ChatGPT) tasked with functioning as additional peer-reviewers to check for errors, suggest improvements, and review spelling and grammar. Any corrections are manually verified. Our preference for em dashes is independent of AI.
Updates.
Our COVID-19 meta-analyses involve the extraction of over 229,000 datapoints from thousands of papers for 227 treatments. We thank the thousands of scientists, physicians, and other contributors that have provided updates, suggestions, feedback, and corrections. These are all welcome and can be submitted at https://c19early.org/azmeta.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.
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Retrospective 848 ICU patients in Saudi Arabia, showing higher mortality with azithromycin in unadjusted results. Submit Corrections or Updates.
Retrospective 185 COVID-19 ICU patients in Saudi Arabia showing higher mortality with HCQ in unadjusted results, and no significant difference with azithromycin. Submit Corrections or Updates.
RCT 60 hospitalized COVID-19 patients evaluating the efficacy and safety of adding oral N-acetylcysteine (NAC) at 600mg three times daily to standard antiviral treatment regimens. There was lower mortality for patients that received azithromycin, without statistical significance. Submit Corrections or Updates.
Late treatmentRCT · ISRCTN86534580 · 1,323 patients · UK · May – Nov 2020
Azithromycin for COVID-19
Lower ventilation with azithromycin
Not statistically significant · p = 0.47
RCT 1,388 outpatients in the UK showing no significant benefit with azithromycin. There was no significant difference in time to first reported recovery or risk of hospitalization or death by 28 days with azithromycin compared to usual care alone. Only 31% of participants had PCR-confirmed SARS-CoV-2 infection.
c19early.org
PRINCIPLE trial selective reporting delays
Results for effective but politically inconvenient treatments were withheld for very long periods.
Treatment patients Duration Results delay
HCQ214 413 2 months Over 5 years214
Azithromycin170 540 6 months 56 days215
Budesonide216 1,073 4 months 12 days217
Doxycycline218 780 5 months 42 days215
Colchicine219 156 3 months 120 days220
Ivermectin41 2,157 14 months 600 days (810 days from ~1,000 per arm enrollment)
Favipiravir221 ~2,250 15 months 780 days (1,000 days from ~1,000 per arm enrollment)
Submit Corrections or Updates.
Late treatmentRCT · NCT04322123 · 667 patients · Brazil · Mar – May 2020
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower mortality and higher ventilation
Not statistically significant · p = 0.17 (mortality) and p = 0.28 (ventilation)
Late stage RCT of 667 hospitalized patients with up to 14 days of symptoms at enrollment and receiving up to 4 liters per minute supplemental oxygen, not finding a significant effect after 15 days.

Authors note: "the trial cannot definitively rule out either a substantial benefit of the trial drugs or a substantial harm", sample sizes are too small.

The paper uses the terms mild and moderate, however all patients had serious enough disease to be hospitalized, and 14% were actually randomized in the ICU.

The trial had significant protocol deviations and unusually low medication adherence.

Authors note: "our aim was to exclude patients already receiving longer and potentially therapeutic doses of the study treatments" in explanation for why the study protocol was changed to exclude patients with previous use of the medications >24hrs. Analyzing these patients rather than excluding them may have revealed effectiveness with early use as shown in other studies.

The trial initially required enrollment within 48 hours of admission and was changed to remove this requirement, this change is likely to reduce effectiveness because enrollment was moved later, compared to the time the disease became serious enough for hospitalization. Total HCQ dosage 5.6g.

A correction for 17 errors has been published222. Submit Corrections or Updates.
Retrospective 3,044 hospitalized COVID-19 patients in Italy, showing no significant difference with azithromycin. 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 723 hospitalized COVID-19 patients in Italy showing no significant difference with azithromycin treatment. Submit Corrections or Updates.
Retrospective 31,260 COVID-19 cases and 125,039 matched controls, showing lower risk of COVID-19 with previous azithromycin use. Submit Corrections or Updates.
Retrospective 3,473 hospitalized patients showing higher mortality with azithromycin, without statistical significance. Authors note the removal of azithromycin from the treatment guidelines in April 2020, introducing confounding by time. Submit Corrections or Updates.
Late treatmentRCT · NCT04321278 · 397 patients · Brazil
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
No significant difference in mortality
Small RCT comparing the addition of AZ for very late stage patients on ventilation or oxygen. One notable result is that even within this extremely late stage population, results suggest increased efficacy with the addition of AZ for patients with earlier use of AZ/HCQ, OR 0.71 [0.25-2.03] (Figure S4).

Patients received 8g of HCQ over 10 days, approaching the high levels used in the RECOVERY trial (9.2g over 10 days), showing significantly more adverse events than typical trials. 50% of patients were on mechanical ventilation at baseline.

More than the increase in mortality at day 29 occurred on day 0, and more than 3x the increase occurred by day 2. Submit Corrections or Updates.
Retrospective 283 patients in the USA showing higher mortality with all treatments (not statistically significant). Confounding by indication is likely. In the supplementary appendix, authors note that the treatments were usually given for patients that required oxygen therapy. Oxygen therapy and ICU admission (possibly, the paper includes ICU admission for model 2 in some places but not others) were the only variables indicating severity used in adjustments. Submit Corrections or Updates.
Late treatmentRCT · 336 patients · Iran · Apr – Aug 2020
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower ventilation with azithromycin
Not statistically significant · p = 0.4
RCT 336 COVID-19 patients with moderate to severe infection showing low-dose prednisolone significantly reduced length of hospital stay compared to lopinavir/ritonavir. There were no significant differences when comparing azithromycin to lopinavir/ritonavir. Submit Corrections or Updates.
Late treatmentRCT · 183 patients · Belgium · Apr 2020 – Dec 2021
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Lower ventilation with azithromycin
Not statistically significant · p = 0.5
RCT 183 hospitalized COVID-19 patients showing no significant differences with azithromycin treatment. Submit Corrections or Updates.
Late treatmentRCT · NCT04381962 · 298 patients · UK · Jun 2020 – Jan 2021
Azithromycin for COVID-19
Lower progression with azithromycin
Not statistically significant · p = 0.24
RCT 298 mild-to-moderate COVID-19 outpatients in the UK showing no significant difference in hospitalization or death with late azithromycin treatment. Treatment was delayed an average of 6 days from onset.

7 vs. 3 hospitalizations occurred by day 1 in the treatment vs. control groups in this open label trial (Figure 2). Submit Corrections or Updates.
Late treatmentRCT · NCT04381936 · 7,763 patients · UK · Apr – Nov 2020
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
primary
no CI
00.511.52+
← Azithromycin
reduces risk
Azithromycin
increases risk →
No significant difference in outcomes seen
RCT 7,763 hospitalized COVID-19 patients showing no significant differences with very late (75% on oxygen at baseline) azithromycin treatment. Only 91% of treatment patients received azithromycin and 17% of control patients received azithromycin or other macrolides. Submit Corrections or Updates.
ProphylaxisRetrospective · 44,046 patients · South Korea
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Azithromycin
reduces risk
Azithromycin
increases risk →
Higher progression and fewer cases
Not statistically significant · p = 0.33 (progression) and p = 0.1 (fewer cases)
Retrospective database analysis showing no significant differences with azithromycin use. Submit Corrections or Updates.
Retrospective 1,235 COVID-19 patients in the DRC, showing lower risk with combined HCQ+AZ treatment. After propensity score matching, treated patients showed significantly better clinical outcomes at day 10 and significantly lower mortality. Submit Corrections or Updates.
Retrospective 1,500 hospitalized late stage (median SaO2 87.7) patients in Turkey, showing no significant difference in mortality with azithromycin treatment. Submit Corrections or Updates.
Late treatmentRetrospective · 928 patients · USA
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Azithromycin
reduces risk
Azithromycin
increases risk →
Higher mortality with azithromycin
Not statistically significant · p = 0.46
Retrospective 928 cancer patients, showing higher mortality with HCQ+AZ. The relative risks of different treatments suggest significant confounding by indication. Authors note that HCQ+AZ might not be the cause of increased mortality, but instead was given to patients with more severe COVID-19. 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.
Independent analysis of the IHU-Mediterranean data223 with 30,423 COVID-19 patients showing significantly lower risk of ICU admission or death with early treatment of hydroxychloroquine plus azithromycin (HCQ-AZ), and with azithromycin, both compared to no treatment. 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.
Late treatmentRCT · 800 patients · USA · May 2020 – Mar 2021
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Higher hospitalization with azithromycin
Not statistically significant · p = 0.16
RCT 263 COVID-19 outpatients showing no significant difference in COVID-19 symptoms at day 14 with a single 1.2g dose of azithromycin vs placebo. Treatment was very late, a median of 7 days after symptom onset (3 days from onset to test results, 3 days to enrollment, 1 day for shipping). Submit Corrections or Updates.
Early treatmentDouble-blind RCT · 304 patients · Qatar · Apr – Aug 2020
Azithromycin for COVID-19
Worse recovery with azithromycin
Not statistically significant · p = 0.5
Low risk patient RCT for HCQ+AZ and HCQ vs. control, not showing any significant differences.

Authors note that the results are not applicable to higher risk patients, that positive PCR may simply reflect detection of inactive (non-infectious) viral remnants, that an alternative dosage regimen may be more effective, and that medication adherence was unknown.

HCQ dosing was 600mg/day for 1 week, therapeutic levels may not be reached for several days. There were no deaths or serious adverse events.

Viral load was already very high at baseline. Submit Corrections or Updates.
Retrospective study of 367 hematology patients with COVID-19 in Spain. Among 216 patients with very severe COVID-19, there was significantly lower mortality with azithromycin treatment. Mortality was also lower with HCQ, but without statistical significance. Submit Corrections or Updates.
Early treatmentRCT · NCT04622891 · 206 patients · Egypt · May – Sep 2020
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
00.511.52+
← Azithromycin
reduces risk
Azithromycin
increases risk →
Faster viral clearance with azithromycin
p < 0.000001
RCT 305 mild COVID-19 patients showing improved recovery and viral clearance with both azithromycin and clarithromycin. Submit Corrections or Updates.
Late treatmentRCT · 111 patients · Iran · Apr – May 2020
Azithromycin for COVID-19
Outcome
Improvement
Relative Risk · 95% CI
Shorter hospitalization with azithromycin
p = 0.02
Randomized controlled trial of 111 hospitalized COVID-19 patients in Iran showing significantly shorter hospital stay, higher oxygen saturation, and lower respiratory rate at discharge with azithromycin plus hydroxychloroquine and lopinavir/ritonavir compared to hydroxychloroquine and lopinavir/ritonavir alone. There were no significant differences in ICU admission, intubation, or mortality, although there was a trend towards lower ICU admission with azithromycin (3.6% vs. 12.7%, p = 0.07). Patients with prior cardiac disease were excluded. The study is limited by the small sample size and open-label design. Submit Corrections or Updates.
Retrospective 1,319 COVID-19 patients in Mali showing lower mortality with azithromycin treatment. Submit Corrections or Updates.
Retrospective 7,158 hospitalized COVID-19 patients in the USA analyzing famotidine treatment, showing no significant difference in mortality with associated azithromycin treatment. Submit Corrections or Updates.
Retrospective 3,462 hospitalized COVID-19 patients across 13 states in Nigiera, showing lower mortality with AZ. Authors note the worse results with a combination of CQ/HCQ and AZ, compared to either alone, may be related to the side effects becoming more significant for late stage patients. 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 azithromycin 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 azithromycin 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. 35. 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 reduction224. 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 PythonMeta225 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 1229. 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 (2.5.4), statsmodels (0.15.0), and plotly (6.9.0). Mixed-effects meta-regression results are computed with R (4.4.0) using the metafor (4.6-0) and rms (6.8-0) packages, and using the most serious sufficiently powered outcome. For all statistical tests, a p-value less than 0.05 was considered statistically significant. Grobid 0.8.2 is used to parse PDF documents.
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 reliability237. 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 issues239. 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 harmD. Hempenius et al. use ROBINS-I to classify 33 studies for HCQ. The two rated as having the lowest risk of bias235,236 are far from the most informative. Both involve very late treatment, providing no information on recommended usage, and ROBINS-I does a very poor job of accounting for the impact of confounding factorsE.
Our quality evaluation focuses on known issues and bias, and the potential impact on outcomes, rather than just the risk of bias. The estimated potential impact of each confounding factor, and the direction of the impact is considered. For example, consider a study that shows significantly lower risk, the value of the study varies significantly if confounding points to an underestimate or an overestimate of efficacy. In one case, the real effect may be null, while the other case provides stronger evidence of efficacy (which may be greater than the study shows). Analysis focusing on the risk of bias, while simpler, may penalize studies for theoretical or technical issues that have no or minimal impact on outcomes. Analysis also depends on the outcome, for example certain issues are less relevant for objective outcomes such as mortality. Inaccurate penalization, and inaccurate high-quality evaluation in the face of known major issues affecting outcomes, increases in significance during a pandemic when immediate recognition of new evidence is critical, and when considering all global studies, as required during a pandemic. Investigators in other countries may have different customs for design, analysis, and reporting, and different English language skills, however they may not be less diligent or have greater bias. Investigators in lower-pharmaceutical-profit countries may have lower bias towards profitable interventions.
We have classified studies as early treatment if most patients are not already at a severe stage at the time of treatment (for example based on oxygen status or lung involvement), and treatment started within 5 days of the onset of symptoms. If studies contain a mix of early treatment and late treatment patients, we consider the treatment time of patients contributing most to the events (for example, consider a study where most patients are treated early but late treatment patients are included, and all mortality events were observed with late treatment patients). We note that a shorter time may be preferable. Antivirals are typically only considered effective when used within a shorter timeframe, for example 0-36 or 0-48 hours for oseltamivir, with longer delays not being effective75,76.
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/azmeta.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.
Lounnas, 2/29/2024, retrospective, France, peer-reviewed, 6 authors, study period March 2020 - December 2021. risk of death/ICU, 27.3% lower, OR 0.73, p < 0.001, adjusted per study, propensity score matching, multivariable, RR approximated with OR.
Omrani, 11/20/2020, Double Blind Randomized Controlled Trial, placebo-controlled, Qatar, peer-reviewed, 19 authors, study period 13 April, 2020 - 1 August, 2020, Q-PROTECT trial. risk of hospitalization, 33.3% higher, RR 1.33, p = 1.00, treatment 4 of 152 (2.6%), control 3 of 152 (2.0%), HCQ+AZ vs. HCQ.
progression to pneumonia, 66.7% lower, RR 0.33, p = 0.62, treatment 1 of 152 (0.7%), control 3 of 152 (2.0%), NNT 76, HCQ+AZ vs. HCQ.
risk of symptomatic at day 21, 100% higher, RR 2.00, p = 0.50, treatment 6 of 152 (3.9%), control 3 of 152 (2.0%), HCQ+AZ vs. HCQ.
relative improvement in Ct, 4.2% worse, RR 1.04, p = 0.63, treatment 152, control 152, HCQ+AZ vs. HCQ, day 6.
Rashad, 8/11/2021, Randomized Controlled Trial, Egypt, peer-reviewed, 10 authors, study period May 2020 - September 2020, trial NCT04622891 (history). risk of no improvement, 25.6% lower, RR 0.74, p = 0.09, treatment 37 of 107 (34.6%), control 46 of 99 (46.5%), NNT 8.4.
time to viral-, 34.1% lower, relative time 0.66, p < 0.001, treatment mean 8.7 (±2.8) n=107, control mean 13.2 (±4.2) n=99.
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.
AlQadheeb, 5/10/2023, retrospective, Saudi Arabia, peer-reviewed, mean age 55.8, 9 authors, study period March 2020 - August 2021. risk of death, 22.2% higher, RR 1.22, p = 0.08, treatment 467 of 775 (60.3%), control 36 of 73 (49.3%).
Alqahtani, 3/12/2025, retrospective, Saudi Arabia, peer-reviewed, mean age 56.7, 15 authors, study period 13 March, 2020 - 13 September, 2020. risk of death, 9.0% lower, OR 0.91, p = 0.85, treatment 159, control 26, RR approximated with OR.
Atefi, 11/20/2023, retrospective, Iran, peer-reviewed, 10 authors, trial IRCT20200623047897N1. risk of death, 85.1% lower, RR 0.15, p = 0.31, treatment 0 of 18 (0.0%), control 4 of 42 (9.5%), NNT 10, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
Butler, 3/31/2021, Randomized Controlled Trial, United Kingdom, peer-reviewed, 18 authors, study period 22 May, 2020 - 30 November, 2020, average treatment delay 6.0 days, trial ISRCTN86534580 (PRINCIPLE). risk of mechanical ventilation, 49.6% lower, RR 0.50, p = 0.47, treatment 2 of 496 (0.4%), control 5 of 625 (0.8%), NNT 252.
risk of ICU admission, 24.2% lower, RR 0.76, p = 1.00, treatment 3 of 495 (0.6%), control 5 of 625 (0.8%), NNT 516.
risk of oxygen therapy, 16.2% lower, RR 0.84, p = 0.69, treatment 10 of 497 (2.0%), control 15 of 625 (2.4%), NNT 258.
risk of hospitalization, 8.5% lower, RR 0.91, p = 0.87, treatment 16 of 500 (3.2%), control 22 of 629 (3.5%), NNT 336, concurrent randomization, day 28, Table S2.
risk of no recovery, 7.4% lower, HR 0.93, p = 0.23, treatment 500, control 823, inverted to make HR<1 favor treatment, first reported recovery.
Cavalcanti, 7/23/2020, Randomized Controlled Trial, Brazil, peer-reviewed, baseline oxygen required 41.8%, 35 authors, study period 29 March, 2020 - 18 May, 2020, trial NCT04322123 (history) (COALITION I). risk of death, 57.0% lower, HR 0.43, p = 0.17, treatment 5 of 172 (2.9%), control 7 of 159 (4.4%), adjusted per study, HCQ+AZ vs. HCQ.
risk of death, 44.5% lower, RR 0.55, p = 0.49, treatment 3 of 172 (1.7%), control 5 of 159 (3.1%), NNT 71, HCQ+AZ vs. HCQ, day 15.
risk of mechanical ventilation, 54.0% higher, HR 1.54, p = 0.28, treatment 19 of 172 (11.0%), control 12 of 159 (7.5%), adjusted per study, HCQ+AZ vs. HCQ.
risk of 7-point scale, 18.0% lower, OR 0.82, p = 0.49, treatment 172, control 159, adjusted per study, HCQ+AZ vs. HCQ, RR approximated with OR.
Corradini, 4/24/2021, retrospective, Italy, peer-reviewed, 60 authors. risk of death, 12.0% higher, OR 1.12, p = 0.38, treatment 222, control 1,479, adjusted per study, Table S6, all patients, multivariable, RR approximated with OR.
Dinoi, 2/20/2025, retrospective, Italy, peer-reviewed, 11 authors, study period 17 March, 2020 - 15 June, 2021. risk of death, 27.7% lower, OR 0.72, p = 0.08, treatment 87 of 247 (35.2%) cases, 106 of 247 (42.9%) controls, NNT 12, case control OR.
Donida, 1/31/2024, retrospective, Italy, peer-reviewed, 4 authors, study period 21 February, 2020 - 31 May, 2020. risk of death, 7.0% lower, HR 0.93, p = 0.79, treatment 180 of 548 (32.8%), control 101 of 175 (57.7%), NNT 4.0, adjusted per study, multivariable, Cox proportional hazards.
Frontera, 10/26/2020, retrospective, USA, preprint, median age 64.0, 14 authors, excluded in exclusion analyses: 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, 22.0% higher, HR 1.22, p = 0.07, treatment 2,014, control 1,459, adjusted per study.
Furtado, 9/4/2020, Randomized Controlled Trial, Brazil, peer-reviewed, 33 authors, average treatment delay 8.0 days, trial NCT04321278 (history) (COALITION II), excluded in exclusion analyses: very late stage patients. risk of death, 8.0% higher, HR 1.08, p = 0.63, treatment 90 of 214 (42.1%), control 73 of 183 (39.9%), day 29.
risk of death, 2.6% higher, RR 1.03, p = 0.91, treatment 66 of 214 (30.8%), control 55 of 183 (30.1%), day 15.
6 point scale, 30.1% lower, OR 0.70, p = 0.08, treatment 214, control 183, inverted to make OR<1 favor treatment, day 29, RR approximated with OR.
6 point scale, 26.5% lower, OR 0.74, p = 0.10, treatment 214, control 183, inverted to make OR<1 favor treatment, day 15, primary outcome, RR approximated with OR.
Gadhiya, 4/8/2021, retrospective, USA, peer-reviewed, 4 authors, excluded in exclusion analyses: substantial unadjusted confounding by indication likely. risk of death, 72.8% higher, RR 1.73, p = 0.15, treatment 43 of 182 (23.6%), control 12 of 101 (11.9%), adjusted per study, odds ratio converted to relative risk, multivariate logistic regression.
Ghanei, 9/15/2021, Randomized Controlled Trial, Iran, peer-reviewed, 18 authors, study period 13 April, 2020 - 9 August, 2020. risk of death, 18.9% lower, RR 0.81, p = 0.79, treatment 10 of 226 (4.4%), control 6 of 110 (5.5%), NNT 97, azithromycin groups vs. lopinavir/ritonavir.
risk of mechanical ventilation, 51.3% lower, RR 0.49, p = 0.40, treatment 3 of 226 (1.3%), control 3 of 110 (2.7%), NNT 71, azithromycin groups vs. lopinavir/ritonavir.
risk of ICU admission, 23.5% lower, RR 0.76, p = 0.61, treatment 11 of 226 (4.9%), control 7 of 110 (6.4%), NNT 67, azithromycin groups vs. lopinavir/ritonavir.
Gyselinck, 1/27/2022, Randomized Controlled Trial, Belgium, peer-reviewed, mean age 62.0, 23 authors, study period 24 April, 2020 - 17 December, 2021, average treatment delay 7.0 days, trial EudraCT-2020-001614-38A. risk of death, 10.9% higher, HR 1.11, p = 0.87, treatment 119, control 64, Kaplan-Meier.
risk of mechanical ventilation, 26.2% lower, HR 0.74, p = 0.50, treatment 119, control 64.
risk of ICU admission, 6.6% higher, HR 1.07, p = 0.85, treatment 119, control 64.
risk of no recovery, 2.2% lower, HR 0.98, p = 0.89, treatment 119, control 64, inverted to make HR<1 favor treatment.
Hinks, 10/31/2021, Randomized Controlled Trial, United Kingdom, peer-reviewed, mean age 45.0, 22 authors, study period 3 June, 2020 - 29 January, 2021, average treatment delay 6.02 days, trial NCT04381962 (history) (ATOMIC2). risk of death, 1.4% higher, RR 1.01, p = 1.00, treatment 1 of 145 (0.7%), control 1 of 147 (0.7%).
risk of death/hospitalization, 1.0% lower, HR 0.99, p = 0.99, treatment 15 of 145 (10.3%), control 17 of 147 (11.6%), NNT 82, Cox proportional hazards, model 3.
risk of death/hospitalization, 8.0% lower, RR 0.92, p = 0.82, treatment 15 of 145 (10.3%), control 17 of 147 (11.6%), NNT 82, adjusted per study, odds ratio converted to relative risk, model 3.
progression to pneumonia, 80.3% lower, RR 0.20, p = 0.24, treatment 0 of 119 (0.0%), control 2 of 114 (1.8%), NNT 57, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
Horby, 2/28/2021, Randomized Controlled Trial, United Kingdom, peer-reviewed, mean age 65.0, 34 authors, study period 7 April, 2020 - 27 November, 2020, average treatment delay 8.0 days, trial NCT04381936 (history) (RECOVERY), excluded in exclusion analyses: very late stage patients. risk of death, 3.0% lower, RR 0.97, p = 0.50, treatment 561 of 2,582 (21.7%), control 1,162 of 5,181 (22.4%), NNT 143, day 28, primary outcome.
risk of mechanical ventilation, 8.0% lower, RR 0.92, p = 0.29, treatment 211 of 2,430 (8.7%), control 461 of 4,881 (9.4%), NNT 131.
Kayembe, 5/7/2021, retrospective, Democratic Republic of Congo, peer-reviewed, 9 authors, study period 10 March, 2020 - 31 August, 2020, this trial uses multiple treatments in the treatment arm (combined with HCQ) - results of individual treatments may vary. risk of death, 47.4% lower, HR 0.53, p = 0.03, treatment 1,100, control 135, inverted to make HR<1 favor treatment, 988 included for analysis, Cox proportional hazards, day 15.
Kokturk, 4/28/2021, retrospective, database analysis, Turkey, peer-reviewed, 68 authors. risk of death, 50.5% higher, RR 1.50, p = 0.47, treatment 34 of 738 (4.6%), control 33 of 762 (4.3%), adjusted per study, odds ratio converted to relative risk.
Kuderer, 5/28/2020, retrospective, USA, peer-reviewed, 73 authors, excluded in exclusion analyses: substantial unadjusted confounding by indication likely. risk of death, 26.8% higher, RR 1.27, p = 0.46, treatment 12 of 93 (12.9%), control 41 of 486 (8.4%), odds ratio converted to relative risk, AZ.
risk of death, 152.0% higher, RR 2.52, p < 0.001, treatment 45 of 181 (24.9%), control 41 of 486 (8.4%), odds ratio converted to relative risk, HCQ+AZ.
Mehrizi, 12/18/2023, retrospective, Iran, peer-reviewed, 10 authors, study period 1 February, 2020 - 20 March, 2022. risk of death, 32.0% lower, OR 0.68, p < 0.001, RR approximated with OR.
Oldenburg, 8/10/2021, Double Blind Randomized Controlled Trial, placebo-controlled, USA, peer-reviewed, median age 43.0, 15 authors, study period 22 May, 2020 - 16 March, 2021, average treatment delay 7.0 days, trial NCT04332107 (history) (ACTION). risk of hospitalization, 788.0% higher, RR 8.88, p = 0.16, treatment 5 of 125 (4.0%), control 0 of 72 (0.0%), continuity correction due to zero event (with reciprocal of the contrasting arm), day 21.
ED visit, 418.4% higher, RR 5.18, p = 0.01, treatment 18 of 125 (14.4%), control 2 of 72 (2.8%), ED visit or urgent care, day 21.
risk of no recovery, 0.8% lower, RR 0.99, p = 1.00, treatment 65 of 131 (49.6%), control 35 of 70 (50.0%), NNT 262, day 21.
risk of transmission, 12.1% lower, RR 0.88, p = 0.66, treatment 33 of 522 (6.3%), control 20 of 278 (7.2%), NNT 115, day 21.
Sekhavati, 10/31/2020, Randomized Controlled Trial, Iran, peer-reviewed, 18 authors, study period 24 April, 2020 - 8 May, 2020. risk of death, 66.9% lower, RR 0.33, p = 0.50, treatment 0 of 56 (0.0%), control 1 of 55 (1.8%), NNT 55, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
risk of mechanical ventilation, 85.8% lower, RR 0.14, p = 0.12, treatment 0 of 56 (0.0%), control 3 of 55 (5.5%), NNT 18, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm).
risk of ICU admission, 71.9% lower, RR 0.28, p = 0.09, treatment 2 of 56 (3.6%), control 7 of 55 (12.7%), NNT 11.
hospitalization time, 22.7% lower, relative time 0.77, p = 0.02, treatment 56, control 55.
Traore, 1/17/2025, retrospective, Mali, peer-reviewed, median age 43.0, 14 authors, study period 27 March, 2020 - 30 June, 2022. risk of death, 69.0% lower, HR 0.31, p = 0.04, adjusted per study, multivariable.
Yeramaneni, 2/28/2021, retrospective, USA, peer-reviewed, 6 authors, study period 11 February, 2020 - 8 May, 2020. risk of death, 7.0% lower, OR 0.93, p = 0.84, treatment 4,003, control 3,155, adjusted per study, multivariable, day 30, RR approximated with OR.
Yilgwan, 5/11/2023, retrospective, Nigeria, peer-reviewed, 12 authors, study period 25 February, 2020 - 30 August, 2021. risk of death, 67.0% lower, OR 0.33, p < 0.001, treatment 1,619, control 1,843, RR approximated with OR.
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.
Dugot, 3/15/2023, retrospective, Israel, peer-reviewed, 7 authors, study period 1 March, 2020 - 31 December, 2020. risk of case, 11.8% lower, OR 0.88, p < 0.001, treatment 1,297 of 31,260 (4.1%) cases, 5,919 of 125,039 (4.7%) controls, NNT 47, adjusted per study, case control OR, multivariable.
Huh, 12/19/2020, retrospective, database analysis, South Korea, peer-reviewed, 8 authors. risk of progression, 53.6% higher, RR 1.54, p = 0.33, treatment 3 of 6 (50.0%), control 875 of 2,799 (31.3%), adjusted per study, odds ratio converted to relative risk, multivariable.
risk of case, 42.0% lower, OR 0.58, p = 0.10, treatment 11 of 7,341 (0.1%) cases, 103 of 36,705 (0.3%) controls, NNT 14, adjusted per study, case control OR, multivariable.
Loucera, 8/16/2022, retrospective, Spain, peer-reviewed, 8 authors, study period January 2020 - November 2020. risk of death, 15.0% lower, HR 0.85, p = 0.005, treatment 2,465, control 13,503, Cox proportional hazards, day 30.
Piñana, 8/25/2020, retrospective, Spain, peer-reviewed, median age 64.0, 46 authors, study period 1 March, 2020 - 15 May, 2020. risk of death, 58.0% lower, OR 0.42, p = 0.02, adjusted per study, multivariable, RR approximated with OR.
Viral infection and replication involves attachment, entry, uncoating and release, genome replication and transcription, translation and protein processing, assembly and budding, and release. Each step can be disrupted by therapeutics.
Monoclonal antibodies were previously included. Other treatments such as dexamethasone, tocilizumab, and baricitinib were recommended for late stage hospitalized patients.
Smoking was known to cause lung cancer since at least 1939, but this was not widely recognized in the US until 1964, 25 years later. Surgeon general Leroy Burney tried publicizing the danger starting in 1957, with limited success. Surgeon general Luther Terry, appointed in 1961, prompted by President Kennedy in 1962 amid pressure from health advocates, finally got recognition in 1964. The 1964 report reviewed 7,000+ studies, but these could (and should) have been reviewed and acted upon in real-time as they were published. Historians attribute the 25 year delay to an industry campaign to manufacture doubt and controversy, through tactics like funding biased and fraudulent research from "independent" organizations, attacking scientists, and political lobbying. The success of the industry campaign is only possible because officials did not analyze the research in detail. Fraudulent industry research supported prior failures, but would have been called out as fraudulent by officials that analyzed and understood the research in real-time.
When administered late in infection, HCQ may enhance viral egress by further increasing lysosomal pH beyond the effect of ORF3a's water channel activity, thereby promoting lysosomal exocytosis, inactivating degradative enzymes, and facilitating the release of SARS-CoV-2 particles into the extracellular environment231,232. Research also suggests potential cardioprotective effects at lower doses, but cardiotoxicity with excessive dosage233. 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.