Povidone-Iodine reduces COVID-19 risk: real-time meta analysis of 21 studies
Abstract
Significantly lower risk is seen for mortality, hospitalization, recovery, cases, and viral clearance. 11 studies from 11 independent teams in 9 countries show significant
benefit.
Meta analysis using the most serious outcome reported shows
51% [38‑61%] lower risk. Results are similar for Randomized Controlled Trials, higher quality studies, and peer-reviewed studies.
Early treatment is more effective than late treatment.
Results are very robust — in exclusion sensitivity analysis 17 of
21 studies must be excluded to avoid finding statistically significant
efficacy in pooled analysis.
3 RCTs
with 424 patients have not reported results (up to 3 years late).
Excessive use of PVP-I could affect thyroid function.
No treatment is 100%
effective. Protocols combine safe and effective options with individual
risk/benefit analysis and monitoring.
Povidone-Iodine may be detrimental to the natural microbiome, raising concern for side effects, especially with prolonged or excessive use.
All data and sources to reproduce this analysis are in the appendix.
Povidone-Iodine for COVID-19 — Highlights
PVP-I reduces
risk with very high confidence for viral clearance and in pooled analysis, and low confidence for mortality, hospitalization, recovery, and cases.
13th treatment shown effective in
February 2021, now with p = 0.0000000011 from 21 studies.
Real-time updates
and corrections with a consistent protocol for 112 treatments. Outcome specific analysis and combined evidence from all
studies including treatment delay, a primary confounding factor.
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 povidone-iodine studies. The marked dates indicate the time when efficacy was known with a statistically significant improvement of ≥10% from ≥3 studies for pooled outcomes, one or more specific outcome, pooled outcomes in RCTs, and one or more specific outcome in RCTs. Efficacy based on specific outcomes was delayed by 1.3 months, compared to using pooled outcomes. Efficacy based on specific outcomes in RCTs was delayed by 1.3 months, compared to using pooled outcomes in RCTs.
Naso/oropharyngeal treatments
AlkalinizationAstodrimer Sodium
Cetylpyridin..
Chlorhexidine
Chlorphenira..
Hydrogen Per..
Iota-carragee..
Nitric Oxide
Phthalocyan..
Plasma-activ..
Povidone-Iod..
Sodium Bicar..
pHOXWELL
SARS-CoV-2 infection typically starts in the upper respiratory
tract, and specifically the nasal respiratory epithelium. Entry via the eyes
and gastrointestinal tract is possible, but less common, and entry via other
routes is rare.
Infection may progress to the lower respiratory tract, other tissues, and the
nervous and cardiovascular systems. The primary initial route for entry into
the central nervous system is thought to be the olfactory nerve in the nasal
cavity3.
Progression may lead to cytokine storm, pneumonia, ARDS, neurological
injury4-15 and cognitive
deficits7,12, cardiovascular
complications16-19, organ failure, and death.
Systemic treatments may be insufficient to prevent
neurological damage11.
Minimizing replication as early as possible is recommended.
Logically, stopping replication in the upper respiratory tract should be
simpler and more effective.
Wu et al., using an airway organoid model incorporating many in
vivo aspects, show that SARS-CoV-2 initially attaches to cilia —
hair-like structures responsible for moving the mucus layer and where ACE2 is
localized in nasal epithelial cells22. The mucus layer and the
need for ciliary transport slow down infection, providing more time for
localized treatments20,21.
Early or prophylactic nasopharyngeal/oropharyngeal treatment may avoid the
consequences of viral replication in other tissues, and avoid the requirement
for systemic treatments with greater potential for side effects.
SARS-CoV-2 infection and replication involves the complex interplay of 50+
host and viral proteins and other factorsA,23-29, providing many
therapeutic targets for which many existing compounds have known activity.
Scientists have predicted that over 8,000 compounds may
reduce COVID-19 risk30, either by
directly minimizing infection or replication, by supporting immune system
function, or by minimizing secondary complications.
We analyze all significant
controlled studies of
povidone-iodine
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 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.
Figure 3. Treatment stages.
Several in vitro studies show that PVP-I is effective
for SARS-CoV-2 at clinically relevant concentrations31-37.
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 4 plots individual results by treatment stage.
Figure 5, 6, 7, 8, 9, 10, and 11
show forest plots for random effects meta-analysis of
all studies with pooled effects, mortality results, hospitalization, recovery, cases, viral clearance, and peer reviewed studies.
| Improvement | Studies | Patients | Authors | |
|---|---|---|---|---|
| All studies | 51% [38‑61%] **** | 21 | 3,202 | 200 |
| After exclusions | 56% [39‑68%] **** | 11 | 2,876 | 102 |
| Peer-reviewed studiesPeer-reviewed | 49% [36‑59%] **** | 18 | 3,108 | 164 |
| Randomized Controlled TrialsRCTs | 53% [38‑65%] **** | 18 | 2,841 | 184 |
| Mortality | 72% [8‑92%] * | 2 | 872 | 12 |
| HospitalizationHosp. | 85% [73‑91%] **** | 2 | 806 | 14 |
| Recovery | 14% [4‑24%] ** | 2 | 224 | 21 |
| Viral | 65% [44‑78%] **** | 19 | 1,572 | 179 |
| RCT viral | 68% [47‑81%] **** | 17 | 1,477 | 169 |
| Early treatment | Late treatment | Prophylaxis | |
|---|---|---|---|
| All studies | 64% [46‑76%] **** | 43% [27‑55%] **** | 45% [20‑62%] ** |
| After exclusions | 67% [41‑82%] *** | 45% [-34‑77%] | 45% [20‑62%] ** |
| Peer-reviewed studiesPeer-reviewed | 63% [41‑77%] **** | 43% [27‑55%] **** | 45% [20‑62%] ** |
| Randomized Controlled TrialsRCTs | 70% [52‑81%] **** | 31% [11‑47%] ** | 45% [20‑62%] ** |
| Mortality | 88% [50‑97%] ** | 57% [31‑73%] *** | |
| HospitalizationHosp. | 85% [73‑91%] **** | ||
| Recovery | 15% [4‑24%] ** | -27% [-528‑74%] | |
| Viral | 72% [50‑84%] **** | 32% [11‑48%] ** | |
| RCT viral | 77% [55‑88%] **** | 32% [11‑48%] ** |
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Figure 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.
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Figure 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.
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Figure 6. Random effects meta-analysis for mortality results.
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Figure 7. Random effects meta-analysis for hospitalization.
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Figure 8. Random effects meta-analysis for recovery.
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Figure 9. Random effects meta-analysis for cases.
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Figure 10. Random effects meta-analysis for viral clearance.
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Figure 11. 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 12 shows a comparison of results for RCTs and non-RCT studies.
Figure 13, 14, and 15
show forest plots for random effects meta-analysis of
all Randomized Controlled Trials, RCT mortality results, and RCT viral clearance results.
RCT results are included in Table 1 and Table 2.
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Figure 12. Results for RCTs and non-RCT studies.
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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.
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Figure 14. Random effects meta-analysis for RCT mortality results.
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Figure 15. Random effects meta-analysis for RCT viral clearance results.
RCTs help to make study groups more similar and can provide a higher level of
evidence, however they are subject to many biases40, and
analysis of double-blind RCTs has identified extreme levels of bias41.
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 112 treatments we have analyzed,
66% 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 112 treatments43.
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 112 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 (B) 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 see47,48.
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.
Figure 16.
Optimal spray angle may increase nasopharyngeal drug delivery 100x for nasal sprays,
adapted from Akash et al.
In addition to the dosage and frequency of administration,
efficacy for nasopharyngeal/oropharyngeal treatments may depend on many
other details. For example considering sprays, viscosity, mucoadhesion,
sprayability, and application angle are important.
Akash et al. performed a computational fluid dynamics study
of nasal spray administration showing 100x improvement in nasopharyngeal drug
delivery using a new spray placement protocol, which involves holding the spay
nozzle as horizontally as possible at the nostril, with a slight tilt towards
the cheeks. The study also found the optimal droplet size range for
nasopharyngeal deposition was ~7-17µm.
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 17 shows a forest plot for random
effects meta-analysis of all studies after exclusions.
Arefin, study only provides short-term viral load results.
Elzein, study only provides short-term viral load results.
Fantozzi, study only provides short-term viral load results.
Ferrer, study only provides short-term viral load results.
Graves, study only provides short-term viral load results.
Natto, study only provides short-term viral load results.
Pablo-Marcos, unadjusted results with no group details.
Seneviratne, study only provides short-term viral load results.
Sevinç Gül, study only provides short-term viral load results.
Sirijatuphat, study only provides short-term viral load results.
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Figure 17. 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 hours63,64. 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 cases65 |
| <24 hours | -33 hours symptoms66 |
| 24-48 hours | -13 hours symptoms66 |
| Inpatients | -2.5 hours to improvement67 |
Figure 18 shows a mixed-effects meta-regression for efficacy
as a function of treatment delay in COVID-19 studies from 112 treatments, showing
that efficacy declines rapidly with treatment delay. Early treatment is
critical for COVID-19.
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Figure 18. Early treatment is more effective. Meta-regression showing efficacy as a function of treatment delay in COVID-19 studies from 112 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
variants69, for example the Gamma variant shows significantly
different characteristics70-73. 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 variants74,75.
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 (B) et al. analyze a treatment from two different manufacturers, showing 9
different impurities, with significantly different concentrations for each
manufacturer.
Across all
studies there is a strong association between different outcomes, for example
improved recovery is strongly associated with lower mortality. However,
efficacy may differ depending on the effect measured, for example a treatment
may be more effective against secondary complications and have minimal effect
on viral clearance.
The
distribution of studies will alter the outcome of a meta analysis. Consider a
simplified example where everything is equal except for the treatment delay,
and effectiveness decreases to zero or below with increasing delay. If there
are many studies using very late treatment, the outcome may be negative, even
though early treatment is very effective.
All meta analyses combine heterogeneous studies, varying in population,
variants, and potentially all factors above, and therefore may obscure
efficacy by including studies where treatment is less effective. Generally, we
expect the estimated effect size from meta analysis to be less than that for
the optimal case.
Looking at all studies is valuable for providing an overview of all research,
important to avoid cherry-picking, and informative when a positive result is
found despite combining less-optimal situations. However, the resulting
estimate does not apply to specific cases such as
early treatment in high-risk populations.
While we present results for all studies, we also present treatment time and
individual outcome analyses, which may be more informative for specific use
cases.
This section validates the use of pooled effects for COVID-19, which enables
earlier detection of efficacy, however pooled effects are no longer required
for povidone-iodine as of March 2021. Efficacy is now known based on specific outcomes for all studies and when restricted to RCTs. Efficacy based on specific outcomes was delayed by 1.3 months compared to using pooled outcomes. Efficacy based on specific outcomes in RCTs was delayed by 1.3 months compared to using pooled outcomes in RCTs.
For COVID-19, delay in clinical results translates into
additional death and morbidity, as well as additional economic and societal
damage. Combining the results of studies reporting different outcomes is
required.
There may be no mortality in a trial with low-risk patients,
however a reduction in severity or improved viral clearance may translate
into lower mortality in a high-risk population.
Different studies may report lower severity, improved recovery, and lower mortality,
and the significance may be very high when combining the results.
"The studies reported different outcomes" is not a good reason for
disregarding results.
Pooling the results of studies reporting different outcomes allows us to use
more of the available information. Logically we should, and do, use additional
information when evaluating treatments—for example dose-response and
treatment delay-response relationships provide additional evidence of efficacy
that is considered when reviewing the evidence for a treatment.
We present both specific outcome and pooled analyses.
In order to combine the results of studies reporting different outcomes we use
the most serious outcome reported in each study, based on the thesis that
improvement in the most serious outcome provides comparable measures of
efficacy for a treatment. A critical advantage of this approach is
simplicity and transparency.
There are many other ways to combine evidence for different outcomes, along
with additional evidence such as dose-response relationships, however these
increase complexity.
Trials with high-risk patients may be restricted due to ethics for treatments
that are known or expected to be effective, and they increase difficulty for
recruiting. Using less severe outcomes as a proxy for more serious outcomes
allows faster and safer collection of evidence.
For many COVID-19 treatments, a reduction in mortality logically
follows from a reduction in hospitalization, which follows from a reduction in
symptomatic cases, which follows from a reduction in PCR positivity. We can
directly test this for COVID-19.
Analysis of the the association between different outcomes across studies from
all 112
treatments we cover confirms the validity of pooled outcome analysis for COVID-19.
Figure 19 shows that lower hospitalization is very strongly associated
with lower mortality (p < 0.000000000001).
Similarly, Figure 20 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 21 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 = 0.00000032 to p = 0.000000011.
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Figure 19. Lower hospitalization is associated with lower mortality, supporting pooled outcome analysis.
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Figure 20. Improved recovery is associated with lower mortality, supporting pooled outcome analysis.
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Figure 19. 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 5.0 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 22 shows when treatments were found effective during the
pandemic. Pooled outcomes often resulted in earlier detection of efficacy.
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Figure 22. 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.
Analysis of short-term changes in viral load using PCR may not detect
effective treatments because PCR is unable to differentiate between intact
infectious virus and non-infectious or destroyed virus particles. For example
Tarragó‐Gil, Alemany perform RCTs with cetylpyridinium chloride
(CPC) mouthwash that show no difference in PCR viral load, however there was
significantly increased detection of SARS-CoV-2 nucleocapsid protein,
indicating viral lysis. CPC inactivates SARS-CoV-2 by degrading its membrane,
exposing the nucleocapsid of the virus. To better estimate changes in viral
load and infectivity, methods like viral culture that can
differentiate intact vs. degraded virus are preferred.
Studies to date use a variety of administration methods to the
respiratory tract, including nasal and oral sprays, nasal irrigation, oral
rinses, and inhalation. Table 4 shows the relative efficacy for
nasal, oral, and combined administration. Combined administration shows the
best results, and nasal administration is more effective than oral. Precise
efficacy depends on the details of administration, e.g., mucoadhesion and
sprayability for sprays.
| Nasal/oral administration to the respiratory tract | Improvement | Studies |
| Oral spray/rinse | 38% [25‑49%] | 11 |
| Nasal spray/rinse | 56% [48‑63%] | 16 |
| Nasal & oral | 91% [74‑97%] | 7 |
Nasopharyngeal/oropharyngeal treatments may not be highly selective. In
addition to inhibiting or disabling SARS-CoV-2, they may also be harmful to
beneficial microbes, disrupting the natural microbiome in the oral cavity and
nasal passages that have important protective and metabolic roles96. This may be
especially important for prolonged use or overuse.
Table 5 summarizes the potential for common
nasopharyngeal/oropharyngeal treatments to affect the natural
microbiome.
| Treatment | Microbiome disruption potential | Notes |
|---|---|---|
| Iota-carrageenan | Low | Primarily antiviral, however extended use may mildly affect the microbiome |
| Nitric Oxide | Low to moderate | More selective towards pathogens, however excessive concentrations or prolonged use may disrupt the balance of bacteria |
| Alkalinization | Moderate | Increases pH, negatively impacting beneficial microbes that thrive in a slightly acidic environment |
| Cetylpyridinium Chloride | Moderate | Quaternary ammonium broad-spectrum antiseptic that can disrupt beneficial and harmful bacteria |
| Phthalocyanine | Moderate to high | Photodynamic compound with antimicrobial activity, likely to affect the microbiome |
| Chlorhexidine | High | Potent antiseptic with broad activity, significantly disrupts the microbiome |
| Hydrogen Peroxide | High | Strong oxidizer, harming both beneficial and harmful microbes |
| Povidone-Iodine | High | Potent broad-spectrum antiseptic harmful to beneficial microbes |
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 results97-100.
For povidone-iodine, 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 23 shows a scatter plot of
results for prospective and retrospective studies.
Prospective studies show 50% [36‑61%] improvement in meta
analysis, compared to 57% [31‑73%] for retrospective
studies, showing no significant difference.
However, there has only been one retrospective study to date.
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Figure 23. 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. Figure 24 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 < 0.05101-108.
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 24. 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. PVP-I for COVID-19
lacks this because it is off-patent, has multiple manufacturers, and is very low cost.
In contrast, most COVID-19 povidone-iodine 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 povidone-iodine 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 alone78-89.
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.
5 of the 21
studies compare against other treatments, which may reduce the effect
seen.
1 of 21 studies
combine treatments. The results of
povidone-iodine
alone may differ.
1 of 18 RCTs use combined treatment.
Other meta analyses show significant improvements with povidone-iodine for viral load1,2 and viral clearance1.
SARS-CoV-2 infection and replication involves a complex
interplay of 50+ host and viral proteins and other
factors23-29, providing many therapeutic
targets.
Over 8,000 compounds have been predicted to reduce COVID-19
risk30, either by directly
minimizing infection or replication, by supporting immune system function, or
by minimizing secondary complications.
Figure 25 shows an overview of the results for povidone-iodine
in the context of multiple COVID-19 treatments, and Figure 26 shows a plot
of efficacy vs. cost for COVID-19 treatments.
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Figure 25.
Scatter plot showing results within the context of multiple COVID-19 treatments.
Diamonds shows the results of random effects meta-analysis.
0.5% of 8,000+ proposed treatments show efficacy118.
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Figure 26. Efficacy vs. cost for COVID-19 treatments.
SARS-CoV-2 infection typically starts in the upper respiratory tract.
Progression may lead to cytokine storm, pneumonia, ARDS, neurological issues,
organ failure, and death. Stopping replication in the upper respiratory tract,
via early or prophylactic nasopharyngeal/oropharyngeal treatment, can avoid
the consequences of progression to other tissues, and avoid the requirement
for systemic treatments with greater potential for side effects.
PVP-I is
an effective treatment for COVID-19.
Significantly lower risk is seen for mortality, hospitalization, recovery, cases, and viral clearance. 11 studies from 11 independent teams in 9 countries show significant
benefit.
Meta analysis using the most serious outcome reported shows
51% [38‑61%] lower risk. Results are similar for Randomized Controlled Trials, higher quality studies, and peer-reviewed studies.
Early treatment is more effective than late treatment.
Results are very robust — in exclusion sensitivity analysis 17 of
21 studies must be excluded to avoid finding statistically significant
efficacy in pooled analysis.
Excessive use of PVP-I could affect thyroid function.
Other meta analyses show significant improvements with povidone-iodine for viral load1,2 and viral clearance1.
Povidone-Iodine may be detrimental to the natural microbiome, raising concern for side effects, especially with prolonged or excessive use.
RCT with 189 patients showing significantly greater viral clearance with a single application of PVP-I. Authors recommend using PVP-I prophylactically in the nasopharynx and oropharynx. NCT04549376119.
RCT 606 patients in Bangladesh for povidone iodine mouthwash/gargle, nasal drops and eye drops showing significantly lower death, hospitalization, and PCR+ at day 7.
RCT with 200 patients and 421 contacts, with 100 patients and their contacts treated with nasal and oropharyngeal sprays containing povidone-iodine and glycyrrhizic acid, showing significantly faster viral clearance and recovery, and significantly lower transmission.
SOC included vitamin C and zinc. The spray active ingredients included a compound of glycyrrhizic acid in the form of ammonium glycyrrhizate 2.5 mg/ml plus PVI 0.5% for oropharyngeal and dipotassium glycyrrhizinate 2.5 mg/ml plus PVI 0.5% for nasal spray. Patients were advised to concomitantly use oropharyngeal and nasal sprays 6 times per day. They were instructed to abstain from food, drink, and smoke for 20min, particularly after oropharyngeal spray. The oropharyngeal spray bottle contains an atomizer that ends with a long arm applicator to insert inside the mouth cavity and can be directed up, down, right, or left to cover the entire pharyngeal area.
SOC included vitamin C and zinc. The spray active ingredients included a compound of glycyrrhizic acid in the form of ammonium glycyrrhizate 2.5 mg/ml plus PVI 0.5% for oropharyngeal and dipotassium glycyrrhizinate 2.5 mg/ml plus PVI 0.5% for nasal spray. Patients were advised to concomitantly use oropharyngeal and nasal sprays 6 times per day. They were instructed to abstain from food, drink, and smoke for 20min, particularly after oropharyngeal spray. The oropharyngeal spray bottle contains an atomizer that ends with a long arm applicator to insert inside the mouth cavity and can be directed up, down, right, or left to cover the entire pharyngeal area.
Small RCT comparing mouthwashing with PVP-I, chlorhexidine, and water, showing significant efficacy for both PVP-I and chlorhexidine, with PVP-I increasing Ct by a mean of 4.45 (p < 0.0001) and chlorhexidine by a mean of 5.69 (p < 0.0001), compared to no significant difference for water.
Mouthrinse RCT in Italy comparing short-term viral load after a single 60 second treatment with povidone-iodine, hydrogen peroxide, chlorhexidine, and saline. The greatest efficacy was seen with povidone-iodine, especially for patients with low viral load at baseline.
Small very late (>50% 7+ days from symptom onset, 9 PVP-I patients) RCT testing mouthwashing with cetylpyridinium chloride, chlorhexidine, povidone-iodine, hydrogen peroxide, and distilled water, showing no significant differences. Over 30% of patients show >90% decrease in viral load @2 hrs with all 5. Authors note that a trend was observed for viral load decrease with PVP-I @2h for patients <6 days from onset (p=0.06, Wilcox test).
RCT 23 early COVID-19 outpatients showing significantly improved reduction in viral load and significantly faster viral clearance with povidone-iodine nasal spray compared to placebo. The study was underpowered due to low recruitment, enrolling only 23 patients from a target of 144. Authors report generally mild symptoms and a 6% benefit over placebo on symptom scores (AUC symptom score days 2–5) without statistical significance, but do not provide details.
Notably, no benefit was seen for rapid antigen test positivity, which is unable to distinguish viable and non-viable virus. The relatively poor diagnostic information from viral positivity using methods that cannot distinguish viable virus may present misleading results in many COVID-19 studies.
Treatment 8 times daily for a total of 20 doses.
Notably, no benefit was seen for rapid antigen test positivity, which is unable to distinguish viable and non-viable virus. The relatively poor diagnostic information from viral positivity using methods that cannot distinguish viable virus may present misleading results in many COVID-19 studies.
Treatment 8 times daily for a total of 20 doses.
Two RCTs with a total of 247 recently diagnosed COVID-19 patients showing a significant reduction in salivary SARS-CoV-2 viral load 30 minutes after rinsing with a cetylpyridinium chloride (CPC) mouthwash compared to rinsing with saline or water. No significant difference was seen 60 minutes post-rinse or with other mouthwashes. Supplementary tables 9 and 10 show that viral load was lower for all treatments at 60 minutes (including saline and water), without statistical significance. Authors only report short-term viral load, no clinical or longer term results are reported. Patients were late stage, 6-7 days post symptoms, when there has likely been significant viral spread to other tissues.
RCT of PCR+ patients with Ct<=20 with 12 treatment and 12 control patients, concluding that nasopharyngeal decolonization may reduce the carriage of infectious SARS-CoV-2 in adults with mild to moderate COVID-19. All patients but 1 had negative viral titer by day 3 (group not specified). There was no significant difference in viral RNA quantification over time. The mean relative difference in viral titers between baseline and day 1 was 75% [43%-95%] in the intervention group and 32% [10%-65%] in the control group. Thyroid dysfunction occurred in 42% of treated patients, with spontaneous resolution after the end of treatment. Patients in the treatment group were younger.
129 patient povidone-iodine early treatment RCT with results not reported over 3 years after completion.
Retrospective 266 COVID-19 ICU patients in India, showing significantly lower mortality with PVP-I oral gargling and topical nasal use, and non-statistically significant higher mortality with ivermectin and lower mortality with remdesivir.
RCT 120 outpatients in Turkey, showing improved reduction in viral load with PVP-I nasal irrigation.
PVP-I prepared with hypertonic alkaline solution had better results.120 show that SARS-CoV-2 requires acidic pH to infect cells, therefore alkalinization may add additional benefits.
All patients received favipiravir. PVP-I 1% 4 times per day.
PVP-I prepared with hypertonic alkaline solution had better results.120 show that SARS-CoV-2 requires acidic pH to infect cells, therefore alkalinization may add additional benefits.
All patients received favipiravir. PVP-I 1% 4 times per day.
245 participant povidone-iodine + chlorhexidine prophylaxis RCT with results not reported over 2 years after completion.
Estimated 50 patient povidone-iodine early treatment RCT with results not reported over 2 years after estimated completion.
RCT 430 COVID+ patients in Japan, showing significantly lower viral infectivity from culture, and significantly faster PCR viral clearance with PVP-I.
For days 2-4 the study compares treatment with PVP-I vs. water (on day 5 both groups received PVP-I). Most patients were asymptomatic. 4 times per day mouthwashing and gargling with 20mL of 15-fold diluted PVP–I 7% or water.
For days 2-4 the study compares treatment with PVP-I vs. water (on day 5 both groups received PVP-I). Most patients were asymptomatic. 4 times per day mouthwashing and gargling with 20mL of 15-fold diluted PVP–I 7% or water.
Tiny RCT with 5 PVP-I patients, gargling 30 seconds, 3x per day, and 5 control patients (essential oils and tap water were also tested), showing improved viral clearance with PVP-I.
60 patient RCT comparing chlorhexidine, PVP-I, and saline in Saudi Arabia with a single mouth rinse treatment and PCR testing 5 minutes later, showing statistically significant improvement in Ct value for PVP-I. PVP-I showed greater improvement than saline, without statistical significance.
Small prospective study with 31 patients gargling povidone-iodine, 17 hydrogen peroxide, and 40 control patients, showing lower viral load mid-recovery with povidone-iodine, without reaching statistical significance. Oropharyngeal only, and only every 8 hours for two days. Results may be better with the addition of nasopharyngeal use, more frequent use, and without the two day limit.
Authors report only one of the 7 previous trials for PVP-I and COVID-19. Non-randomized study with no adjustments or group details. Some results in Figure 1 appear to be switched compared to the text and the labels in the figure. The viral clearance figures do not match the group sizes - for example authors report 62% PCR- for PVP-I at the 3rd test, however there is no number of 31 patients that rounds to 62%.
Authors report only one of the 7 previous trials for PVP-I and COVID-19. Non-randomized study with no adjustments or group details. Some results in Figure 1 appear to be switched compared to the text and the labels in the figure. The viral clearance figures do not match the group sizes - for example authors report 62% PCR- for PVP-I at the 3rd test, however there is no number of 31 patients that rounds to 62%.
Prophylaxis RCT in Singapore with 3,037 low risk patients, showing lower serious cases, lower symptomatic cases, and lower confirmed cases of COVID-19 with all treatments (ivermectin, HCQ, PVP-I, and Zinc + vitamin C) compared to vitamin C.
Meta-analysis of vitamin C in 6 previous trials shows a benefit of 16%, so the actual benefit of ivermectin, HCQ, and PVP-I may be higher. Cluster RCT with 40 clusters.
There were no hospitalizations and no deaths.
Meta-analysis of vitamin C in 6 previous trials shows a benefit of 16%, so the actual benefit of ivermectin, HCQ, and PVP-I may be higher. Cluster RCT with 40 clusters.
There were no hospitalizations and no deaths.
Small mouthwash RCT with 4 PVP-I patients and 2 water patients concluding that PVP-I may have a sustained effect on reducing the salivary SARS-CoV-2 level in COVID-19 patients. ISRCTN95933274.
RCT with 21 PVP-I and 20 saline patients gargling for 30 seconds and testing PCR Ct after 30 minutes, showing greater improvement with PVP-I, without statistical significance.
Ct values differ across testing platforms, however the reported Ct value difference can represent a large difference in viral load. For example, using the calibration included with the ct2vl converter, the reported difference in mean Ct values corresponds to a reduction in viral load of over 3x for PVP-I.
Ct values differ across testing platforms, however the reported Ct value difference can represent a large difference in viral load. For example, using the calibration included with the ct2vl converter, the reported difference in mean Ct values corresponds to a reduction in viral load of over 3x for PVP-I.
Small single-arm trial testing short-term viral load change after a single administration of three puffs of 0.4% PVP-I, showing lower viral titer at 3 minutes and 4 hours, not reaching statistical significance. Authors note that one reason for the lower change compared to in vitro results is that the spray administration may be less effective.
Small mouth rinsing and gargling RCT with 15 1% PVP-I, 12 0.5% PVP-I, 15 3% hydrogen peroxide, 12 1.5% hydrogen peroxide, and 15 water patients, showing rapid improvement in Ct value in all groups, and no significant differences between groups.
Very late treatment (7 days from onset) RCT comparing 11 & 13 PVP-I (0.5% and 2%), and 11 saline spray patients in the USA, showing no significant differences. There was no control group (saline is likely not a placebo, showing efficacy in other trials). There are large unadjusted differences between groups, e.g. 7.1 days from onset for PVP-I versus 4.8 for saline. Baseline Ct was higher for PVP-I, providing less room for improvement. Authors note that they cannot determine if earlier use is more beneficial.
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 povidone-iodine 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 povidone-iodine 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 to121.
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 1124.
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
(3.13.1) 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 PythonMeta125
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 effective63,64.
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/pmeta.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.
| Arefin, 5/18/2021, Randomized Controlled Trial, Bangladesh, peer-reviewed, 9 authors, study period 1 July, 2020 - 30 October, 2020, trial NCT04549376 (history), excluded in exclusion analyses: study only provides short-term viral load results. | risk of no viral clearance, 78.9% lower, RR 0.21, p = 0.02, treatment 4 of 27 (14.8%), control 19 of 27 (70.4%), NNT 1.8, 0.6% nasal irrigation. |
| risk of no viral clearance, 89.5% lower, RR 0.11, p < 0.001, treatment 2 of 27 (7.4%), control 19 of 27 (70.4%), NNT 1.6, 0.5% nasal irrigation. | |
| risk of no viral clearance, 52.6% lower, RR 0.47, p = 0.006, treatment 9 of 27 (33.3%), control 19 of 27 (70.4%), NNT 2.7, 0.4% nasal irrigation. | |
| risk of no viral clearance, 80.0% lower, RR 0.20, p < 0.001, treatment 5 of 27 (18.5%), control 25 of 27 (92.6%), NNT 1.4, 0.6% nasal spray. | |
| risk of no viral clearance, 64.0% lower, RR 0.36, p < 0.001, treatment 9 of 27 (33.3%), control 25 of 27 (92.6%), NNT 1.7, 0.5% nasal spray. | |
| risk of no viral clearance, 73.6% lower, RR 0.26, p < 0.001, treatment 29 of 135 (21.5%), control 44 of 54 (81.5%), NNT 1.7, all treatment vs. all control. | |
| Choudhury, 12/3/2020, Randomized Controlled Trial, Bangladesh, peer-reviewed, 6 authors, study period 1 February, 2020 - 30 August, 2020. | risk of death, 88.2% lower, RR 0.12, p < 0.001, treatment 2 of 303 (0.7%), control 17 of 303 (5.6%), NNT 20. |
| risk of hospitalization, 84.4% lower, RR 0.16, p < 0.001, treatment 12 of 303 (4.0%), control 77 of 303 (25.4%), NNT 4.7. | |
| risk of no viral clearance, 96.2% lower, RR 0.04, p < 0.001, treatment 8 of 303 (2.6%), control 213 of 303 (70.3%), NNT 1.5, day 7. | |
| Elsersy, 4/19/2022, Double Blind Randomized Controlled Trial, placebo-controlled, Egypt, peer-reviewed, 8 authors, study period March 2021 - July 2021, this trial uses multiple treatments in the treatment arm (combined with glycyrrhizic acid) - results of individual treatments may vary, trial PACTR202101875903773. | risk of hospitalization, 90.9% lower, RR 0.09, p = 0.06, treatment 0 of 100 (0.0%), control 5 of 100 (5.0%), NNT 20, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm). |
| recovery time, 14.6% lower, relative time 0.85, p = 0.008, treatment mean 7.6 (±2.0) n=100, control mean 8.9 (±2.0) n=100. | |
| recovery time, 49.1% lower, relative time 0.51, p < 0.001, treatment mean 5.6 (±1.3) n=100, control mean 11.0 (±3.4) n=100, smell. | |
| recovery time, 48.2% lower, relative time 0.52, p < 0.001, treatment mean 5.7 (±1.0) n=100, control mean 11.0 (±4.0) n=100, taste. | |
| risk of no viral clearance, 67.7% lower, RR 0.32, p < 0.001, treatment 21 of 100 (21.0%), control 65 of 100 (65.0%), NNT 2.3, mid-recovery, day 7. | |
| risk of no viral clearance, 90.0% lower, RR 0.10, p = 0.010, treatment 1 of 100 (1.0%), control 10 of 100 (10.0%), NNT 11, day 10. | |
| risk of no viral clearance, 29.3% lower, RR 0.71, p < 0.001, treatment 70 of 100 (70.0%), control 99 of 100 (99.0%), NNT 3.4, day 4. | |
| risk of transmission, 91.9% lower, RR 0.08, p < 0.001, treatment 12 of 194 (6.2%), control 173 of 227 (76.2%), NNT 1.4, symptomatic. | |
| risk of transmission, 94.0% lower, RR 0.06, p < 0.001, treatment 8 of 194 (4.1%), control 157 of 227 (69.2%), NNT 1.5, PCR+. | |
| Elzein, 3/17/2021, Double Blind Randomized Controlled Trial, Lebanon, peer-reviewed, 7 authors, study period June 2020 - September 2020, excluded in exclusion analyses: study only provides short-term viral load results. | relative improvement in Ct value, 88.8% better, RR 0.11, p < 0.05, treatment 25, control 9. |
| Friedland, 3/30/2024, Double Blind Randomized Controlled Trial, placebo-controlled, South Africa, peer-reviewed, 2 authors, trial ACTRN12618001244291. | relative viral clearance rate, 59.5% better, RR 0.40, p = 0.03, treatment 10, control 13. |
| relative LSM log10TCID50 AUC2-4 reduction, 52.0% better, RR 0.48, p = 0.03, treatment 10, control 13. | |
| Guenezan, 2/4/2021, Randomized Controlled Trial, France, peer-reviewed, 7 authors, study period 1 September, 2020 - 23 October, 2020, trial NCT04371965 (history). | relative improvement in viral titer reduction between baseline and day 1, 63.2% better, RR 0.37, p = 0.25, treatment 12, control 12. | Jacox, 10/20/2021, Double Blind Randomized Controlled Trial, USA, trial NCT04584684 (history) (MOR). | 129 patient RCT with results unknown and over 3 years late. |
| Karaaltin, 10/26/2022, Randomized Controlled Trial, Turkey, preprint, 16 authors, study period September 2021 - October 2021, average treatment delay 1.0 days. | viral load, 83.1% lower, relative load 0.17, p = 0.007, treatment 30, control 30, relative change in viral load, PVP-I vs. control, day 5. |
| viral load, 85.5% lower, relative load 0.14, p = 0.001, treatment 30, control 30, relative change in viral load, PVP-I + HANI vs. control, day 5. | |
| viral load, 82.1% lower, relative load 0.18, p = 0.14, treatment 30, control 30, relative change in viral load, PVP-I vs. control, day 3. | |
| viral load, 90.8% lower, relative load 0.09, p < 0.001, treatment 30, control 30, relative change in viral load, PVP-I + HANI vs. control, day 3. | Khan, 7/31/2022, Double Blind Randomized Controlled Trial, Pakistan, trial NCT04341688 (history) (GARGLES). | Estimated 50 patient RCT with results unknown and over 2 years late. |
| Matsuyama, 11/28/2022, Randomized Controlled Trial, Japan, peer-reviewed, mean age 45.1, 4 authors, study period 30 November, 2020 - 17 March, 2021, trial jRCT1051200078. | viral infectivity, 69.0% lower, RR 0.31, p = 0.03, treatment 4 of 139 (2.9%), control 13 of 140 (9.3%), NNT 16, viral infectivity from culture, day 5. |
| risk of no viral clearance, 38.0% lower, HR 0.62, p = 0.01, treatment 139, control 140, inverted to make HR<1 favor treatment, day 5, primary outcome. | |
| Mohamed, 9/9/2020, Randomized Controlled Trial, Malaysia, preprint, 16 authors, study period 22 June, 2020 - 29 June, 2020, trial NCT04410159 (history). | risk of no viral clearance, 85.7% lower, RR 0.14, p = 0.17, treatment 0 of 5 (0.0%), control 3 of 5 (60.0%), NNT 1.7, relative risk is not 0 because of continuity correction due to zero events (with reciprocal of the contrasting arm), day 12. |
| Natto, 7/29/2022, Randomized Controlled Trial, Saudi Arabia, peer-reviewed, 7 authors, study period June 2021 - July 2021, this trial compares with another treatment - results may be better when compared to placebo, trial NCT04941131 (history), excluded in exclusion analyses: study only provides short-term viral load results. | risk of viral load, 73.6% lower, RR 0.26, p = 0.27, treatment 12, control 12, relative improvement in Ct value, both genes combined. |
| risk of viral load, 96.2% lower, RR 0.04, p = 0.12, treatment mean 4.43 (±4.78) n=12, control mean 0.17 (±7.67) n=12, relative improvement in Ct value, E gene. | |
| risk of viral load, 44.4% lower, RR 0.56, p = 0.60, treatment mean 3.33 (±5.6) n=12, control mean 1.85 (±7.68) n=12, relative improvement in Ct value, S gene. | |
| Pablo-Marcos, 10/25/2021, prospective, Spain, peer-reviewed, mean age 43.0, 6 authors, study period May 2020 - November 2020, excluded in exclusion analyses: unadjusted results with no group details. | relative viral load, 29.2% better, RR 0.71, p = 0.40, treatment 31, control 40, 3rd PCR (mid-recovery). |
| relative viral load, 9.1% better, RR 0.91, p = 0.91, treatment 31, control 40, 4th PCR (most patients recovered). | |
| Sevinç Gül, 7/29/2022, Randomized Controlled Trial, Turkey, peer-reviewed, 4 authors, study period 1 September, 2021 - 1 December, 2021, this trial compares with another treatment - results may be better when compared to placebo, trial NCT05214196 (history), excluded in exclusion analyses: study only provides short-term viral load results. | risk of viral load, 99.5% lower, RR 0.005, p = 0.37, treatment mean 1.85 (±7.06) n=21, control mean 0.01 (±5.89) n=20, relative improvement in Ct value. |
| Sirijatuphat, 8/22/2022, prospective, Thailand, preprint, median age 34.0, 4 authors, study period 15 February, 2021 - 15 March, 2021, trial TCTR20210125002, excluded in exclusion analyses: study only provides short-term viral load results. | viral load, 33.3% lower, relative load 0.67, p = 0.58, after median 2560 IQR 17790 n=12, before median 3840 IQR 9600 n=12, before values 640.0 640.0 40960.0 2560.0 10240.0 10240.0 640.0 2560.0 10240.0 5120.0 40960.0 640.0, after values 10.0 40.0 2560.0 40960.0 5120.0 1280.0 160.0 2560.0 40960.0 40960.0 10240.0 40.0, relative median viral titer, 3 min, left vs. baseline, Mann-Whitney, Table 3. |
| viral load, 87.5% lower, relative load 0.12, p = 0.04, after median 480 IQR 4340 n=12, before median 3840 IQR 9600 n=12, before values 640.0 640.0 40960.0 2560.0 10240.0 10240.0 640.0 2560.0 10240.0 5120.0 40960.0 640.0, after values 80.0 160.0 10240.0 320.0 320.0 10240.0 40.0 640.0 640.0 40960.0 2560.0 0.0, relative median viral titer, 3 min, right vs. baseline, Mann-Whitney, Table 3. | |
| viral load, 83.3% lower, relative load 0.17, p = 0.11, after median 640 IQR 6240 n=12, before median 3840 IQR 9600 n=12, before values 640.0 640.0 40960.0 2560.0 10240.0 10240.0 640.0 2560.0 10240.0 5120.0 40960.0 640.0, after values 160.0 10.0 10240.0 640.0 160.0 1280.0 320.0 640.0 5120.0 40960.0 20480.0 0.0, relative median viral titer, 4 hours, right vs. baseline, Mann-Whitney, Table 3. | |
| Sulistyani, 3/15/2022, Single Blind Randomized Controlled Trial, Indonesia, peer-reviewed, 9 authors, study period July 2021 - September 2021. | relative improvement in Ct value, 6.3% better, RR 0.94, p = 0.74, treatment mean 12.9 (±5.96) n=15, control mean 12.09 (±7.38) n=15, 1% PVP-I vs. water, day 5. |
| relative improvement in Ct value, 11.3% better, RR 0.89, p = 0.54, treatment mean 13.63 (±6.28) n=15, control mean 12.09 (±7.38) n=15, 0.5% PVP-I vs. water, day 5. |
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.
| Fantozzi, 7/28/2022, Randomized Controlled Trial, Italy, peer-reviewed, 14 authors, study period December 2020 - May 2021, this trial compares with another treatment - results may be better when compared to placebo, excluded in exclusion analyses: study only provides short-term viral load results. | risk of no viral clearance, 31.2% lower, RR 0.69, p = 0.26, treatment 5 of 8 (62.5%), control 10 of 11 (90.9%), NNT 3.5, T2. |
| risk of no viral clearance, 58.7% lower, RR 0.41, p = 0.04, treatment 3 of 8 (37.5%), control 10 of 11 (90.9%), NNT 1.9, T1. | |
| Ferrer, 12/22/2021, Randomized Controlled Trial, Spain, peer-reviewed, 19 authors, excluded in exclusion analyses: study only provides short-term viral load results. | relative viral load reduction, 34.0% better, RR 0.66, p = 0.82, treatment 9, control 12, PVP-I vs. water, data from Table S1. |
| relative viral load T4 vs. T1, 93.0% better, RR 0.07, p = 0.35, treatment 9, control 9, data from Table S1. | |
| Graves, 12/9/2024, Double Blind Randomized Controlled Trial, USA, peer-reviewed, mean age 36.0, 16 authors, trial NCT04584684 (history), excluded in exclusion analyses: study only provides short-term viral load results. | viral load, 84.6% lower, relative load 0.15, p = 0.65, treatment 16, control 16, N1/N2 combined. |
| viral load, 84.0% lower, relative load 0.16, p = 0.72, treatment mean 278.66 (±3412.46) n=16, control mean 1737.15 (±15737.8) n=16, N1, 60 min vs. baseline, transformed from log to original scale. | |
| viral load, 86.1% lower, relative load 0.14, p = 0.80, treatment mean 170.72 (±3121.62) n=16, control mean 1224.15 (±16572.36) n=16, N2, 60 min vs. baseline, transformed from log to original scale. | |
| Jamir, 12/13/2021, retrospective, India, peer-reviewed, 6 authors, study period June 2020 - October 2020. | risk of death, 57.0% lower, HR 0.43, p < 0.001, treatment 39 of 163 (23.9%), control 62 of 103 (60.2%), NNT 2.8, adjusted per study, multivariable, Cox proportional hazards. |
| Seneviratne, 12/14/2020, Randomized Controlled Trial, Singapore, peer-reviewed, 12 authors, study period June 2020 - August 2020, excluded in exclusion analyses: study only provides short-term viral load results. | relative fold change, 32.9% better, RR 0.67, p < 0.01, treatment 4, control 2, PVP-I vs. water, 6 hours. |
| Zarabanda, 11/1/2021, Randomized Controlled Trial, USA, peer-reviewed, 13 authors, average treatment delay 7.0 days, this trial compares with another treatment - results may be better when compared to placebo. | risk of no recovery, 26.9% higher, RR 1.27, p = 1.00, treatment 3 of 13 (23.1%), control 2 of 11 (18.2%), 2%. |
| risk of no recovery, 50.0% higher, RR 1.50, p = 1.00, treatment 3 of 11 (27.3%), control 2 of 11 (18.2%), 0.5%. | |
| risk of no viral clearance, no change, RR 1.00, p = 1.00, treatment 2 of 7 (28.6%), control 2 of 7 (28.6%), day 5, minus strand PCR. |
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.
| Keating, 6/30/2022, Randomized Controlled Trial, USA, this trial uses multiple treatments in the treatment arm (combined with chlorhexidine) - results of individual treatments may vary, trial NCT04478019 (history) (SHIELD). | 245 patient RCT with results unknown and over 2 years late. |
| Seet, 4/14/2021, Cluster Randomized Controlled Trial, Singapore, peer-reviewed, 15 authors, study period 13 May, 2020 - 31 August, 2020, this trial compares with another treatment - results may be better when compared to placebo, trial NCT04446104 (history). | risk of symptomatic case, 44.7% lower, RR 0.55, p = 0.002, treatment 42 of 735 (5.7%), control 64 of 619 (10.3%), NNT 22. |
| risk of case, 31.1% lower, RR 0.69, p = 0.01, treatment 338 of 735 (46.0%), control 433 of 619 (70.0%), NNT 4.2, adjusted per study, odds ratio converted to relative risk, model 6. |
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.
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