Azvudine for COVID-19: real-time meta analysis of 26 studies
Abstract
Statistically significant lower risk is seen for mortality, progression, and viral clearance. 19 studies from 16 independent teams in 2 countries show significant
improvements.
Meta analysis using the most serious outcome reported shows
31% [19‑41%] lower risk. Results are similar for Randomized Controlled Trials, higher quality studies, and peer-reviewed studies.
Results are robust — in exclusion sensitivity analysis 13 of 26
studies must be excluded to avoid finding statistically significant efficacy
in pooled analysis.
No treatment or intervention
is 100% effective. All practical, effective, and safe means should be used
based on risk/benefit analysis.
Multiple treatments are typically used
in combination, and other treatments
may be more effective.
Azvudine for COVID-19 — Highlights
Azvudine reduces
risk with very high confidence for mortality, progression, viral clearance, and in pooled analysis, and very low confidence for ICU admission and hospitalization.
44th treatment shown effective with ≥3 clinical studies in
July 2023, now with p = 0.000011 from 26 studies.
Outcome specific analyses and combined evidence from all
studies, incorporating treatment delay, a primary confounding factor.
Real-time updates and corrections,
transparent analysis with all results in the same format, consistent protocol
for 109
treatments.
Figure 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 azvudine studies. The marked dates indicate the time when efficacy was known with a statistically significant improvement of ≥10% from ≥3 studies for pooled outcomes and one or more specific outcome.
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 injury5-15 and
cognitive deficits7,12, cardiovascular
complications16-18, organ failure, and death.
Minimizing replication as early as possible is recommended.
SARS-CoV-2 infection and replication involves the complex interplay of 50+
host and viral proteins and other factorsA,19-24, providing many
therapeutic targets for which many existing compounds have known activity.
Scientists have predicted that over 8,000 compounds may
reduce COVID-19 risk25, either by
directly minimizing infection or replication, by supporting immune system
function, or by minimizing secondary complications.
We analyze all significant
controlled studies of
azvudine
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.
Figure 2 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.
Figure 2. Treatment stages.
An In Silico study supports the efficacy of azvudine26.
An In Vitro study supports the efficacy of azvudine26.
An In Vivo animal study supports the efficacy of azvudine26.
Preclinical research is an important part of the development of
treatments, however results may be very different in clinical trials.
Preclinical results are not used in this paper.
Table 1 summarizes the results for all stages combined, for Randomized Controlled Trials, for peer-reviewed studies, after exclusions, and for specific outcomes.
Table 2 shows results by treatment stage.
Figure 3 plots individual results by treatment stage.
Figure 4, 5, 6, 7, 8, 9, 10, 11, and 12
show forest plots for random effects meta-analysis of
all studies with pooled effects, mortality results, ventilation, ICU admission, hospitalization, progression, recovery, viral clearance, and peer reviewed studies.
| Improvement | Studies | Patients | Authors | |
|---|---|---|---|---|
| All studies | 31% [19‑41%] **** | 26 | 25,201 | 268 |
| After exclusions | 33% [20‑43%] **** | 24 | 24,713 | 254 |
| Peer-reviewed studiesPeer-reviewed | 30% [15‑42%] *** | 21 | 18,717 | 213 |
| Randomized Controlled TrialsRCTs | 27% [-215‑83%] | 1 | 179 | 12 |
| Mortality | 33% [20‑44%] **** | 19 | 23,836 | 216 |
| VentilationVent. | 20% [-50‑57%] | 5 | 2,729 | 39 |
| ICU admissionICU | 20% [-16‑45%] | 7 | 2,992 | 57 |
| HospitalizationHosp. | 11% [-4‑25%] | 3 | 1,494 | 24 |
| Recovery | 2% [-8‑11%] | 4 | 1,156 | 44 |
| Viral | 17% [7‑26%] ** | 4 | 679 | 31 |
| Early treatment | Late treatment | |
|---|---|---|
| All studies | 37% [-3‑62%] | 30% [18‑41%] **** |
| After exclusions | 37% [-3‑62%] | 32% [19‑43%] **** |
| Peer-reviewed studiesPeer-reviewed | 44% [-15‑73%] | 29% [14‑41%] *** |
| Randomized Controlled TrialsRCTs | 27% [-215‑83%] | |
| Mortality | 53% [9‑75%] * | 30% [15‑42%] *** |
| VentilationVent. | 20% [-50‑57%] | |
| ICU admissionICU | 20% [-16‑45%] | |
| HospitalizationHosp. | 75% [2‑94%] * | 9% [1‑17%] * |
| Recovery | 2% [-8‑11%] | 42% [-136‑86%] |
| Viral | 32% [1‑53%] * | 15% [5‑25%] ** |
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Figure 3. 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.
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Figure 4. 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.
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Figure 5. Random effects meta-analysis for mortality results.
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Figure 6. Random effects meta-analysis for ventilation.
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Figure 7. Random effects meta-analysis for ICU admission.
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Figure 8. Random effects meta-analysis for hospitalization.
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Figure 9. Random effects meta-analysis for progression.
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Figure 10. Random effects meta-analysis for recovery.
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Figure 11. Random effects meta-analysis for viral clearance.
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Figure 12. Random effects meta-analysis for peer reviewed studies.
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.
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.
Figure 13 shows a forest plot for random
effects meta-analysis of all Randomized Controlled Trials.
RCT results are included in Table 1 and Table 2.
Currently there is only one RCT.
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Figure 13. 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.
RCTs help to make study groups more similar and can provide a higher level of
evidence, however they are subject to many biases29, and
analysis of double-blind RCTs has identified extreme levels of bias30.
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 interests closely aligned with pharmaceutical
companies. 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. 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 109 treatments we have analyzed,
65% 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.
For COVID-19, observational study results do not systematically
differ from RCTs, RR 1.00 [0.92‑1.08]
across 109 treatments32.
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 109 treatments
we cover, showing no significant difference in the results of RCTs compared to
observational studies, RR 1.00 [0.92‑1.08]. Similar results are found for all low-cost treatments, RR
1.02 [0.92‑1.12]. High-cost treatments
show a non-significant trend towards RCTs showing greater efficacy,
RR 0.92 [0.82‑1.03].
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 see36,37.
Currently, 48 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, 60% have been confirmed in RCTs, with a mean delay of 7.1 months (68% with 8.2 months delay for low-cost treatments). The remaining treatments either have no RCTs, or the point estimate is consistent.
We need to
evaluate each trial on its own merits. 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.
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.
Figure 14 shows a forest plot for random
effects meta-analysis of all studies after exclusions.
Peng, unadjusted results with no group details.
Zhou, substantial unadjusted confounding by indication likely; unadjusted results with no group details.
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Figure 14. 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.
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 hours40,41.
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.
| Treatment delay | Result |
| Post-exposure prophylaxis | 86% fewer cases42 |
| <24 hours | -33 hours symptoms43 |
| 24-48 hours | -13 hours symptoms43 |
| Inpatients | -2.5 hours to improvement44 |
Figure 15 shows a mixed-effects meta-regression for efficacy
as a function of treatment delay in COVID-19 studies from 109 treatments, showing
that efficacy declines rapidly with treatment delay. Early treatment is
critical for COVID-19.
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Figure 15. Early treatment is more effective. Meta-regression showing efficacy as a function of treatment delay in COVID-19 studies from 109 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 variants46, for
example the Gamma variant shows significantly different characteristics47-50. 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 variants51,52.
Effectiveness may depend strongly on the dosage and treatment regimen.
The use
of other treatments may significantly affect outcomes, including supplements,
other medications, or other interventions such as prone positioning.
Treatments may be synergistic53-64, therefore
efficacy may depend strongly on combined treatments.
The
quality of medications may vary significantly between manufacturers and
production batches, which may significantly affect efficacy and safety.
Williams et al. analyze ivermectin from 11 different sources, showing
highly variable antiparasitic efficacy across different manufacturers.
Xu et al. analyze a treatment from two different manufacturers, showing 9
different impurities, with significantly different concentrations for each
manufacturer.
Across all
studies there is a strong association between different outcomes, for example
improved recovery is strongly associated with lower mortality. However,
efficacy may differ depending on the effect measured, for example a treatment
may be more effective against secondary complications and have minimal effect
on viral clearance.
The
distribution of studies will alter the outcome of a meta analysis. Consider a
simplified example where everything is equal except for the treatment delay,
and effectiveness decreases to zero or below with increasing delay. If there
are many studies using very late treatment, the outcome may be negative, even
though early treatment is very effective.
All meta analyses combine heterogeneous studies, varying in population,
variants, and potentially all factors above, and therefore may obscure
efficacy by including studies where treatment is less effective. Generally, we
expect the estimated effect size from meta analysis to be less than that for
the optimal case.
Looking at all studies is valuable for providing an overview of all research,
important to avoid cherry-picking, and informative when a positive result is
found despite combining less-optimal situations. However, the resulting
estimate does not apply to specific cases such as
early treatment in high-risk populations.
While we present results for all studies, we also present treatment time and
individual outcome analyses, which may be more informative for specific use
cases.
This section validates the use of pooled effects for COVID-19, which enables
earlier detection of efficacy, however note that pooled effects are no longer
required for azvudine as of July 2023.
Efficacy is now known based on specific outcomes.
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.
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.
Another way to view pooled analysis is that we are using more of
the available information. Logically we should, and do, use additional
information. For example dose-response and
treatment delay-response relationships provide significant additional evidence
of efficacy that is considered when reviewing the evidence for a
treatment.
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 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 109
treatments we cover confirms the validity of pooled outcome analysis for COVID-19.
Figure 16 shows that lower hospitalization is very strongly associated
with lower mortality (p < 0.000000000001).
Similarly, Figure 17 shows that improved recovery is very strongly associated
with lower mortality (p < 0.000000000001).
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.
Figure 18 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 = 0.00000042 to p = 0.00000002.
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Figure 16. Lower hospitalization is associated with lower mortality, supporting pooled outcome analysis.
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Figure 17. Improved recovery is associated with lower mortality, supporting pooled outcome analysis.
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Figure 16. Improved viral clearance is associated with fewer serious outcomes, supporting pooled outcome analysis.
Currently, 48 of the treatments we analyze show statistically significant efficacy or harm, defined as ≥10% decreased risk or >0% increased risk from ≥3 studies. 89% of these have been confirmed with one or more specific outcomes, with a mean delay of 5.1 months. When restricting to RCTs only, 56% of treatments showing statistically significant efficacy/harm with pooled effects have been confirmed with one or more specific outcomes, with a mean delay of 6.4 months.
Figure 19 shows when treatments were found effective during the
pandemic. Pooled outcomes often resulted in earlier detection of efficacy.
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Figure 19. 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 difference in treatment delay is 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.
Publishing is often biased
towards positive results. Trials with patented drugs may have a financial conflict of interest that
results in positive studies being more likely to be published, or bias towards more positive results. For example with molnupiravir, trials with negative results remain unpublished to
date (CTRI/2021/05/033864 and CTRI/2021/08/0354242).
For azvudine, there is currently not
enough data to evaluate publication bias with high confidence.
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.
Figure 20 shows a scatter plot of
results for prospective and retrospective studies.
71% of retrospective studies
report a statistically significant positive effect for
one or more outcomes, compared to
100% of prospective studies, consistent with a bias toward publishing negative results.
The median effect size for
retrospective studies is 34% improvement,
compared to 35% for prospective
studies, showing similar results.
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Figure 20. Prospective vs. retrospective studies.
The diamonds show the results of random effects meta-analysis.
Studies for azvudine were primarily late treatment studies, in
contrast with typical patented treatments that were tested with early
treatment as recommended.
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Figure 21. Patented treatments received mostly early treatment studies, while low cost treatments were typically tested for late treatment.
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. Figure 22 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 < 0.0568-75.
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.
Figure 22. Example funnel plot analysis for simulated perfect trials.
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 alone53-64.
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.
SARS-CoV-2 infection and replication involves a complex interplay of 50+ host
and viral proteins and other factors19-24,
providing many therapeutic targets.
Over 8,000 compounds have been predicted to reduce COVID-19
risk25, either by directly
minimizing infection or replication, by supporting immune system function, or
by minimizing secondary complications.
Figure 23 shows an overview of the results for azvudine
in the context of multiple COVID-19 treatments, and Figure 24 shows a plot
of efficacy vs. cost for COVID-19 treatments.
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Figure 23.
Scatter plot showing results within the context of multiple COVID-19 treatments.
Diamonds shows the results of random effects meta-analysis.
0.6% of 8,000+ proposed treatments show efficacy76.
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Figure 24. Efficacy vs. cost for COVID-19 treatments.
Azvudine is
an effective treatment for COVID-19.
Statistically significant lower risk is seen for mortality, progression, and viral clearance. 19 studies from 16 independent teams in 2 countries show significant
improvements.
Meta analysis using the most serious outcome reported shows
31% [19‑41%] lower risk. Results are similar for Randomized Controlled Trials, higher quality studies, and peer-reviewed studies.
Results are robust — in exclusion sensitivity analysis 13 of 26
studies must be excluded to avoid finding statistically significant efficacy
in pooled analysis.
Chen:
Retrospective 207 COVID-19 patients in China, showing azvudine associated with faster viral clearance, with azvudine-treated patients obtaining a negative PCR test result 1.7 days faster on average compared to supportive care alone after adjusting for age and sex.
Chen (B):
PSM retrospective 332 hospitalized moderate to critically ill COVID-19 patients with myocardial injury in China, showing improved 14 day mortality but no difference in overall in-hospital mortality with azvudine treatment.
de Souza:
RCT 179 hospitalized patients in Brazil, showing improved recovery with azvudine treatment.
Dian:
Retrospective 2,118 hospitalized COVID-19 patients in China, showing improved results with azvudine vs. paxlovid.
Han:
PSM retrospective 6,218 hospitalized COVID-19 patients in China showing lower 28-day all-cause mortality with azvudine treatment compared to controls (HR 0.63, 95% CI 0.40-1.00). Subgroup analysis found significantly faster clinical improvement when azvudine was initiated within 5 days of symptom onset compared to controls.
Jin:
Retrospective 481 low-risk COVID-19 patients in China showing no significant difference in recovery or symptomatic severity with azvudine, but slightly lower total viral load.
Li (B):
PSM retrospective 84 hospitalized COVID-19 patients with pre-existing cancer in China, showing faster viral clearance with azvudine. There was no significant difference in length of hospital stay or ICU admission.
Li (C):
Retrospective 4,201 hospitalized COVID-19 patients in China, showing lower mortality with azvudine.
Liu:
Retrospective 148 hospitalized kidney transplant patients with COVID-19 in China showing lower risk of disease progression with azvudine treatment compared, and higher risk with paxlovid treatment.
Liu (B):
Retrospective 572 fully vaccinated hospitalized patients in China, showing lower risk with azvudine treatment, without statistical significance. The composite outcome included intubation, non-invasive respiratory support, ICU admission, and all-cause death. Azvudine was not included in the multivariable analysis (only combined antiviral therapy was used without explanation).
Lv (B):
Retrospective 324 hospitalized kidney transplant recipients with COVID-19 showing no significant benefit with molnupiravir, paxlovid, or azvudine. The study was conducted during the omicron wave in China between December 2022 and January 2023. Adjusted results are only provided for all antivirals combined, however the results are similar before and after adjustment. Multivariable Cox regression analysis for all antivirals combined showed an adjusted hazard ratio for mortality of 6.06, p=0.099. While adjustment includes factors related to baseline severity, there may be residual confounding by indication.
Peng:
Retrospective 166 hospitalized NSCLC patients with COVID-19 showing no significant difference in mortality with paxlovid or azvudine in univariate analysis.
Ren:
PSM retrospective 32,864 hospitalized COVID-19 patients in China showing lower all-cause mortality and disease progression with azvudine treatment.
Shao:
Retrospective 1,082 severely and critically ill COVID-19 patients in China showing lower 60 day mortality with azvudine. Mortality was also lower with paxlovid, but without statistical significance, and health related quality of life was significantly lower for paxlovid patients at 60 days.
Shen:
PSM retrospective 900 hospitalized COVID-19 patients in China showing lower risk of disease progression and death with azvudine treatment.
Sun:
PSM retrospective 490 hospitalized COVID-19 patients with pre-existing conditions in China showing that azvudine was associated with a significantly lower risk of the composite outcome of disease progression, driven largely by lower rates of non-invasive respiratory support. However, there was no significant difference in all-cause mortality or other individual outcomes like ICU admission or invasive mechanical ventilation between the azvudine and control groups.
Wang (B):
Retrospective 249 elderly patients with severe COVID-19, 128 treated with azvudine, 66 treated with paxlovid, and 55 receiving neither treatment, showing no significant differences for Ct value changes, progression, or survival for either treatment. Early viral decline was faster with paxlovid, without statistical significance.
Wei:
PSM retrospective 725 hospitalized COVID-19 patients in China compared the effectiveness and safety of the oral antivirals azvudine and paxlovid. There was no significant difference in the risk of disease progression between groups, but azvudine was associated with lower ICU admission and invasive ventilation use.
Wu:
Retrospective 351 hospitalized COVID-19 patients with pre-existing cardiovascular diseases in China, showing lower mortality with azvudine treatment.
Xu (B):
Retrospective 264 hospitalized COVID-19 patients in China showing lower risk of composite disease progression and all-cause mortality with azvudine treatment.
Yang (B):
PSM retrospective 804 high-risk, nonhospitalized adults with mild to moderate COVID-19 in China. The study compared outcomes between 317 patients who received azvudine with 487 patients who received standard supportive treatment only. The azvudine group had a lower rate of disease progression (composite of death or COVID-19 hospitalization) at 28 days, as well as a lower rate of COVID-19 hospitalization specifically after adjusting for factors. In addition, azvudine shortened the duration of fever if given within 3 days of symptom onset. However, azvudine treatment was associated with a higher incidence of adverse effects, including mainly mild gastrointestinal and nervous system effects.
Zhang:
Prospective multicenter study of 209 severe hospitalized COVID-19 patients in China showing improved 28-day composite outcomes, faster viral clearance, and higher PaO2/FiO2 levels with azvudine plus dexamethasone compared to dexamethasone alone.
Zhang (B):
PSM retrospective 303 hospitalized patients treated with azvudine and 303 matched controls in China, showing shorter hospital stay and higher lymphocyte improvement rate, particularly for non-severe patients, however there were no significant differences for mortality, ICU admission, or mechanical ventilation.
Zhong:
Retrospective 2,862 hospitalized COVID-19 patients in China showing lower mortality with azvudine treatment.
Zhou:
Retrospective 322 hospitalized patients ≥65 in China, showing lower mortality with azvudine treatment, without statistical significance.
Zong:
PSM retrospective 1072 hospitalized patients with COVID-19 pneumonia in China, showing lower mortality with azvudine treatment.
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.
Search terms are azvudine 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 azvudine 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.
This is a living analysis and is updated regularly.
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
both reported, the effect for mortality is used, this may be different to the
effect that a study focused on.
If symptomatic
results are reported at multiple times, we used 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 test status. 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.
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.
When results provide an odds ratio, we compute the relative risk when
possible, or convert to a relative risk according to101.
Reported confidence intervals and p-values were used when available,
using adjusted values 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 1104.
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
(3.13.0) with
scipy (1.14.1), pythonmeta (1.26), numpy (1.26.4), statsmodels (0.14.4), and plotly (5.24.1).
Forest plots are computed using PythonMeta105
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.
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 0.8.0 is used to parse PDF documents.
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 effective40,41.
We received no funding, this research is done in our spare
time. We have no affiliations with any pharmaceutical companies or political
parties.
A summary of study results is below. Please submit
updates and corrections at https://c19early.org/azvmeta.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.
| Chen, 1/6/2023, retrospective, China, preprint, 7 authors, study period August 2022 - October 2022. | recovery time, 12.5% higher, relative time 1.12, p = 0.94, treatment 66, control 41. |
| risk of no viral clearance, 31.6% lower, HR 0.68, p = 0.04, treatment 166, control 41, adjusted per study, inverted to make HR<1 favor treatment, multivariable, Cox proportional hazards. | |
| Han, 7/14/2023, retrospective, China, preprint, 22 authors, study period 10 December, 2022 - 20 February, 2023. | risk of death, 37.0% lower, HR 0.63, p = 0.048, treatment 428, control 428, propensity score matching. |
| risk of no improvement, 2.9% lower, HR 0.97, p = 0.73, treatment 428, control 428, inverted to make HR<1 favor treatment, propensity score matching. | |
| Jin, 2/12/2024, retrospective, China, peer-reviewed, 14 authors. | recovery time, 0.7% higher, relative time 1.01, p = 0.90, treatment mean 12.21 (±2.84) n=33, control mean 12.12 (±2.82) n=33. |
| Wang (B), 2/9/2024, retrospective, China, peer-reviewed, 47 authors. | risk of death, 20.1% lower, HR 0.80, p = 0.44, treatment 128, control 55, adjusted per study, multivariable, Cox proportional hazards. |
| risk of progression, 3.0% lower, HR 0.97, p = 0.91, treatment 128, control 55, adjusted per study, ICU, mechanical ventilation, or death, multivariable, Cox proportional hazards. | |
| Wu, 3/27/2024, retrospective, China, peer-reviewed, 7 authors, average treatment delay 2.0 days. | risk of death, 81.1% lower, HR 0.19, p < 0.001, treatment 90, control 90, adjusted per study, propensity score matching, multivariable, Cox proportional hazards. |
| risk of death, 56.9% lower, HR 0.43, p = 0.002, treatment 106, control 245, adjusted per study, multivariable, Cox proportional hazards. | |
| Yang (B), 7/20/2023, retrospective, China, peer-reviewed, 11 authors, study period 19 December, 2022 - 5 January, 2023. | risk of death, 90.8% lower, RR 0.09, p = 0.09, treatment 0 of 317 (0.0%), control 6 of 487 (1.2%), NNT 81, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| risk of hospitalization, 74.8% lower, RR 0.25, p = 0.047, treatment 317, control 487, propensity score weighting. | |
| risk of no recovery, 16.0% lower, RR 0.84, p = 0.19, treatment 317, control 487, propensity score weighting. |
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.
| Chen (B), 4/30/2023, retrospective, China, peer-reviewed, 9 authors. | risk of death, 6.5% lower, RR 0.94, p = 0.88, treatment 29 of 99 (29.3%), control 31 of 99 (31.3%), NNT 49, in-hospital mortality, propensity score matching. |
| risk of death, 63.0% lower, HR 0.37, p = 0.007, treatment 99, control 99, propensity score matching, day 14. | |
| de Souza, 10/19/2023, Double Blind Randomized Controlled Trial, placebo-controlled, Brazil, peer-reviewed, median age 48.0, 12 authors, study period April 2021 - May 2022, trial NCT04668235 (history). | risk of ICU admission, 27.5% lower, RR 0.73, p = 0.72, treatment 3 of 91 (3.3%), control 4 of 88 (4.5%), NNT 80. |
| risk of no hospital discharge, 42.0% lower, RR 0.58, p = 0.49, treatment 3 of 91 (3.3%), control 5 of 88 (5.7%), NNT 42. | |
| relative final score, 81.8% better, RR 0.18, p = 0.01, treatment mean 0.02 (±0.15) n=91, control mean 0.11 (±0.31) n=88. | |
| time to viral-, 13.0% lower, relative time 0.87, p = 0.03, treatment 91, control 88. | |
| Dian, 8/31/2023, retrospective, China, peer-reviewed, 5 authors, study period 5 December, 2022 - 31 January, 2023, this trial compares with another treatment - results may be better when compared to placebo. | risk of death, 63.6% lower, RR 0.36, p = 0.11, treatment 4 of 228 (1.8%), control 11 of 228 (4.8%), NNT 33, propensity score matching. |
| risk of mechanical ventilation, 66.7% lower, RR 0.33, p = 0.28, treatment 2 of 228 (0.9%), control 6 of 228 (2.6%), NNT 57, propensity score matching. | |
| risk of ICU admission, no change, RR 1.00, p = 1.00, treatment 1 of 228 (0.4%), control 1 of 228 (0.4%), propensity score matching. | |
| composite outcome, 48.4% lower, RR 0.52, p = 0.03, treatment 16 of 228 (7.0%), control 31 of 228 (13.6%), NNT 15, non-invasive respiratory support, endotracheal intubation, ICU admission, all-cause death, propensity score matching. | |
| respiratory support, 44.4% lower, RR 0.56, p = 0.07, treatment 15 of 228 (6.6%), control 27 of 228 (11.8%), NNT 19, propensity score matching. | |
| Li (B), 3/4/2024, retrospective, China, peer-reviewed, 6 authors. | risk of ICU admission, 50.0% lower, RR 0.50, p = 0.68, treatment 2 of 42 (4.8%), control 4 of 42 (9.5%), NNT 21. |
| hospitalization time, 11.1% lower, relative time 0.89, p = 0.26, treatment 42, control 42. | |
| risk of no viral clearance, 49.8% lower, HR 0.50, p = 0.03, treatment 42, control 42, adjusted per study, inverted to make HR<1 favor treatment, multivariable, Cox proportional hazards. | |
| risk of no viral clearance, 31.8% lower, RR 0.68, p = 0.19, treatment 15 of 42 (35.7%), control 22 of 42 (52.4%), NNT 6.0. | |
| Li (C), 1/5/2024, retrospective, China, preprint, 7 authors, study period 1 November, 2022 - 31 May, 2023, trial NCT06006611 (history). | risk of death, 29.2% lower, HR 0.71, p = 0.03, treatment 1,103, control 1,103, propensity score matching, Cox proportional hazards. |
| Liu, 4/30/2024, retrospective, China, peer-reviewed, 3 authors, study period 1 December, 2022 - 19 January, 2023. | risk of progression, 45.1% lower, HR 0.55, p = 0.36, inverted to make HR<1 favor treatment, propensity score matching, Cox proportional hazards. |
| Liu (B), 10/21/2023, retrospective, China, peer-reviewed, 4 authors, study period 5 December, 2022 - 31 January, 2023. | risk of progression, 24.1% lower, RR 0.76, p = 0.44, treatment 12 of 126 (9.5%), control 56 of 446 (12.6%), NNT 33, intubation, non-invasive respiratory support, ICU admission, and all-cause death. |
| Lv (B), 6/24/2024, retrospective, China, peer-reviewed, 10 authors, average treatment delay 14.0 days. | risk of death, 42.3% higher, RR 1.42, p = 0.64, treatment 2 of 11 (18.2%), control 40 of 313 (12.8%). |
| Peng, 1/31/2024, retrospective, China, peer-reviewed, 8 authors, study period 12 December, 2022 - 15 January, 2023, excluded in exclusion analyses: unadjusted results with no group details. | risk of death, 13.0% higher, OR 1.13, p = 0.85, treatment 42, control 124, RR approximated with OR. |
| Ren, 11/17/2024, retrospective, China, peer-reviewed, 22 authors, study period 5 December, 2022 - 31 January, 2023, trial NCT06349655 (history). | risk of death, 32.0% lower, HR 0.68, p < 0.001, treatment 5,735, control 5,735, adjusted per study, propensity score matching, multivariable, Cox proportional hazards, RR approximated with OR. |
| risk of progression, 12.0% lower, HR 0.88, p = 0.01, treatment 5,735, control 5,735, adjusted per study, progression to severe disease or death, propensity score matching, multivariable, Cox proportional hazards, RR approximated with OR. | |
| Shao, 7/23/2023, retrospective, China, peer-reviewed, 9 authors, study period 8 December, 2022 - 9 February, 2023. | risk of death, 56.0% lower, HR 0.44, p = 0.007, treatment 177, control 509, adjusted per study, day 60. |
| Shen, 1/23/2023, retrospective, China, preprint, 12 authors, average treatment delay 8.2 days. | risk of death, 74.0% lower, HR 0.26, p = 0.04, treatment 3 of 226 (1.3%), control 10 of 226 (4.4%), NNT 32, propensity score matching, Cox proportional hazards. |
| risk of mechanical ventilation, 90.9% lower, RR 0.09, p = 0.06, treatment 0 of 226 (0.0%), control 5 of 226 (2.2%), NNT 45, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm), propensity score matching. | |
| risk of ICU admission, 75.0% lower, RR 0.25, p = 0.37, treatment 1 of 226 (0.4%), control 4 of 226 (1.8%), NNT 75, propensity score matching. | |
| risk of progression, 57.0% lower, HR 0.43, p = 0.048, treatment 8 of 226 (3.5%), control 17 of 226 (7.5%), NNT 25, all-cause death, intensive care unit admission, initiation of invasive mechanical ventilation, and need for high-flow oxygen therapy, propensity score matching, Cox proportional hazards. | |
| Sun, 5/5/2023, retrospective, China, peer-reviewed, 7 authors, study period 5 December, 2022 - 31 January, 2023. | risk of death, 54.1% lower, HR 0.46, p = 0.16, treatment 5 of 245 (2.0%), control 9 of 245 (3.7%), NNT 61, odds ratio converted to relative risk, Cox proportional hazards. |
| risk of mechanical ventilation, no change, RR 1.00, p = 1.00, treatment 2 of 245 (0.8%), control 2 of 245 (0.8%). | |
| risk of ICU admission, 100% higher, RR 2.00, p = 1.00, treatment 2 of 245 (0.8%), control 1 of 245 (0.4%). | |
| risk of oxygen therapy, 38.5% lower, RR 0.62, p = 0.15, treatment 16 of 245 (6.5%), control 26 of 245 (10.6%), NNT 25. | |
| risk of progression, 47.6% lower, HR 0.52, p = 0.02, treatment 17 of 245 (6.9%), control 31 of 245 (12.7%), NNT 18, odds ratio converted to relative risk, non-invasive respiratory support, endotracheal intubation, ICU admission, and all-cause death, Cox proportional hazards, primary outcome. | |
| Wei, 10/13/2023, retrospective, China, peer-reviewed, 8 authors, study period 1 December, 2022 - 31 January, 2023, this trial compares with another treatment - results may be better when compared to placebo. | risk of death, 0.2% higher, RR 1.00, p = 1.00, treatment 63 of 461 (13.7%), control 36 of 264 (13.6%). |
| risk of mechanical ventilation, 27.7% lower, RR 0.72, p = 0.04, treatment 77 of 461 (16.7%), control 61 of 264 (23.1%), NNT 16. | |
| risk of ICU admission, 55.0% lower, RR 0.45, p = 0.05, treatment 11 of 461 (2.4%), control 14 of 264 (5.3%), NNT 34. | |
| risk of progression, 22.1% lower, RR 0.78, p = 0.07, treatment 98 of 461 (21.3%), control 72 of 264 (27.3%), NNT 17, ICU admission, invasive mechanical ventilation, and in-hospital death, primary outcome. | |
| Xu (B), 11/7/2024, retrospective, China, peer-reviewed, 6 authors, study period 1 December, 2022 - 31 January, 2023. | risk of death, 75.0% lower, HR 0.25, p = 0.02, treatment 132, control 132, adjusted per study, propensity score matching, multivariable. |
| risk of progression, 63.0% lower, HR 0.37, p = 0.02, treatment 132, control 132, adjusted per study, respiratory support, ICU admission, or death, propensity score matching, multivariable. | |
| Zhang, 11/22/2024, prospective, China, peer-reviewed, 6 authors, study period 15 December, 2022 - 30 April, 2023. | risk of progression, 42.6% lower, RR 0.57, p = 0.03, treatment 28 of 165 (17.0%), control 13 of 44 (29.5%), NNT 8.0, death, ICU, or mechanical ventilation, day 28. |
| time to viral-, 14.4% lower, relative time 0.86, p = 0.02, treatment 165, control 44. | |
| Zhang (B), 10/7/2024, retrospective, China, peer-reviewed, mean age 68.8, 7 authors, study period 10 December, 2022 - 10 January, 2023. | risk of death, 32.4% higher, RR 1.32, p = 0.20, treatment 49 of 303 (16.2%), control 37 of 303 (12.2%). |
| risk of mechanical ventilation, 61.5% higher, RR 1.62, p = 0.22, treatment 21 of 303 (6.9%), control 13 of 303 (4.3%). | |
| risk of ICU admission, 7.1% higher, RR 1.07, p = 0.89, treatment 30 of 303 (9.9%), control 28 of 303 (9.2%). | |
| hospitalization time, 9.1% lower, relative time 0.91, p = 0.046, treatment mean 8.34 (±4.79) n=303, control mean 9.17 (±6.25) n=303, all patients. | |
| hospitalization time, 19.3% lower, relative time 0.81, p = 0.001, treatment mean 8.07 (±4.35) n=165, control mean 10.0 (±6.29) n=181, non-severe patients. | |
| Zhong, 4/1/2024, retrospective, China, preprint, 7 authors, study period 1 December, 2022 - 31 March, 2023. | risk of death, 35.0% lower, HR 0.65, p = 0.048, treatment 1,490, control 1,373, propensity score weighting, day 28. |
| risk of death, 52.0% lower, HR 0.48, p = 0.001, treatment 1,490, control 1,373, propensity score weighting, day 14. | |
| risk of death, 87.0% lower, HR 0.13, p = 0.001, treatment 1,490, control 1,373, propensity score weighting, day 7. | |
| Zhou, 10/12/2023, retrospective, China, peer-reviewed, median age 81.0, 6 authors, study period 1 December, 2022 - 31 January, 2023, excluded in exclusion analyses: substantial unadjusted confounding by indication likely; unadjusted results with no group details. | risk of death, 21.8% lower, RR 0.78, p = 0.15, treatment 37 of 131 (28.2%), control 69 of 191 (36.1%), NNT 13. |
| Zong, 7/13/2023, retrospective, China, peer-reviewed, 6 authors, study period 8 December, 2022 - 20 January, 2023. | risk of death, 62.5% lower, OR 0.38, p < 0.001, treatment 195, control 390, propensity score matching, RR approximated with OR. |
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