TRIAL DESIGN AND OVERSIGHT

We conducted this three-group trial at 55 hospitals in Brazil. The trial was designed by the executive committee (see the Supplementary Appendix, available with the full text of this article at NEJM.org) and approved by the Brazilian National Commission for Research Ethics, the Brazilian Health Regulatory Agency (ANVISA), and ethics committees at the participating sites. The trial was funded by the hospitals and research institutes participating in Coalition Covid-19 Brazil (see the Supplementary Appendix).

EMS Pharma provided additional funding and logistic support for the trial and also donated and supplied the trial drugs. EMS Pharma had no role in the conduct of the trial, the analysis, or the decision to submit the manuscript for publication.

The trial was overseen by an independent international data and safety monitoring committee. The executive committee vouches for the completeness and accuracy of the data and for the fidelity of the trial to the protocol (available at NEJM.org).

PARTICIPANTS

The trial included consecutive patients who were 18 years of age or older and who had been hospitalized with suspected or confirmed Covid-19 with 14 or fewer days since symptom onset.

Among the reasons for exclusion from the trial were the use of supplemental oxygen at a rate of more than 4 liters per minute as administered by a nasal cannula or at a level of at least 40% as administered by a Venturi mask; the use of supplemental oxygen administered by a high-flow nasal cannula or invasive or noninvasive ventilation; previous use of chloroquine, hydroxychloroquine, azithromycin, or any other macrolide for more than 24 hours before enrollment (and since the onset of symptoms); and a history of severe ventricular tachycardia or electrocardiographic findings with a corrected QT interval (QTc) of at least 480 msec.

Complete information on the inclusion and exclusion criteria is provided in the Supplementary Appendix. All the patients provided written or electronic informed consent before randomization.

RANDOMIZATION, INTERVENTIONS, AND FOLLOW-UP

Patients were randomly assigned in a 1:1:1 ratio to receive standard care (control group), standard care plus hydroxychloroquine at a dose of 400 mg twice daily for 7 days (hydroxychloroquine-alone group), or standard care plus hydroxychloroquine at a dose of 400 mg twice daily plus azithromycin at a dose of 500 mg once a day for 7 days.

Randomization was performed in blocks of six and was stratified according to the use or nonuse of supplemental oxygen at the time of randomization. Randomization was performed centrally by means of an electronic case-report form system (RedCap) as described in the Supplementary Appendix.¹²

The current standard care for Covid-19 was at the discretion of the treating physicians. The use of glucocorticoids, other immunomodulators, antibiotic agents, and antiviral agents was allowed (see the Supplementary Appendix).

The administration of hydroxychloroquine or chloroquine was not allowed in the control group, and the use of macrolides was not allowed in the control group or the hydroxychloroquine-alone group. Guidance was provided to the investigators about how to adjust or interrupt treatment according to side effects and laboratory abnormalities.

Data were collected daily, from randomization until day 15, in the electronic case-report form. For patients who were discharged before day 15, a structured telephone call to the patient or the patient’s family was conducted on or after day 15 by an interviewer who was unaware of the assigned trial group in order to assess vital status and return to routine activities.

OUTCOMES

The primary outcome was clinical status at 15 days, evaluated with the use of a seven-level ordinal scale. Scores on the scale were defined as follows: a score of 1 indicated not hospitalized with no limitations on activities; 2, not hospitalized but with limitations on activities; 3, hospitalized and not receiving supplemental oxygen; 4, hospitalized and receiving supplemental oxygen; 5, hospitalized and receiving oxygen supplementation administered by a high-flow nasal cannula or noninvasive ventilation; 6, hospitalized and receiving mechanical ventilation; and 7, death.

Secondary outcomes included clinical status at 7 days, evaluated with the use of a six-level ordinal scale (see below and see the Supplementary Appendix); an indication for intubation within 15 days; the receipt of supplemental oxygen administered by a high-flow nasal cannula or noninvasive ventilation between randomization and 15 days; duration of hospital stay; in-hospital death; thromboembolic complications; acute kidney injury; and the number of days alive and free from respiratory support up to 15 days.

A day alive and free from respiratory support was defined as any day in which the patient did not receive supplemental oxygen or invasive or noninvasive mechanical ventilation, from randomization to day 15. Patients who died during the 15-day window were assigned a value of 0 days alive and free from respiratory support in this assessment.

Safety outcomes are listed in the Supplementary Appendix. All the trial outcomes were assessed by the site investigators, who were aware of the trial-group assignments (except as noted above for patients who had been discharged before day 15 and who were assessed for the primary outcome by means of a blinded telephone interview). No formal adjudication of trial outcomes was performed.

SAMPLE-SIZE CALCULATION AND PROTOCOL CHANGES

We had originally planned for the trial to include 630 patients, using the intention-to-treat analysis population, with a six-level ordinal outcome as the primary outcome, as described in the Supplementary Appendix.

However, before the first interim analysis was conducted, we changed the primary-outcome assessment to the seven-level ordinal scale and the main analysis population from the intention-to-treat population to a modified intention-to-treat population that included only patients with a diagnosis of Covid-19 that had been confirmed by reverse-transcriptase–polymerase-chain-reaction (RT-PCR) testing (using the test available at each site).

The change to the use of the seven-level ordinal scale was adopted because on April 10, 2020 (before the first enrolled patient had reached 15 days of follow-up), we established the capability to obtain 15-day information on limitations on activities with the use of blinded telephone interviews.

We therefore added another level to the six-level ordinal outcome, dividing the first level (not hospitalized) into two levels (level 1, not hospitalized and with no limitations on activities; and level 2, not hospitalized but with limitations on activities).

The change to the modified intention-to-treat population was adopted because, under the hypothesis that treatment would have beneficial effects on the primary outcome only for patients who had a confirmed diagnosis, the inclusion of unconfirmed cases would decrease the estimated effect size and power.

s a related change, we added external adjudication of unconfirmed cases, which were classified as probable, possible, or probably not Covid-19 (see the Supplementary Appendix).

The sample size was revised with the use of the overall distribution of the seven-level ordinal outcome at day 15 observed among the first 120 patients, with the levels 1 through 7 having the following proportions of patients: 60%, 19%, 7%, 1%, 1%, 5%, and 7%, respectively.

With 630 patients who had undergone randomization and 510 patients included in the modified intention-to-treat analysis, we calculated that the trial would have 80% power to detect an odds ratio of 0.5 between groups (two-by-two comparisons), at a significance level of 5% and with Bonferroni adjustment for multiple comparisons (α=5%, divided by 3 for each comparison).¹³

STATISTICAL ANALYSIS

The primary outcome was analyzed by mixed ordinal logistic regression with random intercept according to site, assuming proportional odds. We report all two-by-two comparisons. Binary outcomes were assessed with the use of a mixed logistic-regression model, except for in-hospital mortality, which was assessed with a Cox proportional-hazards model.

Continuous outcomes were evaluated by means of generalized linear regression or mixed models for repeated variables, as appropriate. All models were adjusted for age and the use of supplemental oxygen at admission.

We also performed sensitivity analyses that included all the patients who had undergone randomization (intention-to-treat population) and sensitivity analyses for the primary outcome for the following groups: patients with definitive, probable, or possible Covid-19; and patients with definitive or probable Covid-19.

Two additional populations were considered. An efficacy population included patients with a confirmed diagnosis who received at least one dose of the assigned trial drug. The safety population included patients according to the medications received, regardless of the assigned trial group or the result of Covid-19 testing.

We planned three interim analyses, to be conducted when 120 patients, 315 patients, and 504 patients had completed 15 days of follow-up. However, only the first interim analysis was conducted. Owing to faster-than-expected enrollment, primary-outcome data for the second and third interim analyses were available only after trial recruitment was finished. After discussion with the data and safety monitoring committee, the second and third interim analyses were cancelled.

The data and safety monitoring committee used Haybittle–Peto¹⁴ stopping boundaries, with a P-value threshold of less than 0.001 to interrupt the trial for safety and a P-value threshold of less than 0.0001 to interrupt the trial for efficacy. We did not adjust the final values of the hypothesis test for sequential analyses.

Analyses were performed with the use of R software (R Core Team).¹⁵ P values for the primary outcome were adjusted with the use of Bonferroni correction. No P values are reported for secondary outcomes; the widths of the confidence intervals for the secondary outcomes have not been adjusted for multiple comparisons, so the intervals should not be used to infer definitive treatment effects.

P values for the safety analyses were not adjusted given the importance of identifying potential signals of harm. Additional details about the statistical analyses are provided in the Supplementary Appendix.

CHARACTERISTICS OF THE PATIENTS

We recruited 667 patients, including 504 patients with confirmed Covid-19. The numbers of enrolled patients according to site are presented in Table S1 in the Supplementary Appendix. A total of 217 patients were randomly assigned to receive hydroxychloroquine plus azithromycin, 221 to receive hydroxychloroquine, and 229 to receive standard care (control group) (Fig. S1).

The first patient underwent randomization on March 29, 2020; the last patient underwent randomization on May 17, 2020; and follow-up was completed on June 2, 2020. Two patients were excluded after randomization (1 withdrew consent after randomization and 1 had been enrolled twice). The 15-day follow-up was completed for all the remaining 665 patients.

Table 1.Characteristics of the Patients at Baseline (Intention-to-Treat Population).

The characteristics of the patients are shown in Table 1 and Table S2. Most patients (584 patients [87.8%]) underwent randomization within 10 days after symptom onset. The mean age of the patients was 50 years, and 58% of all the included patients were men. A total of 42% of the patients were receiving supplemental oxygen at baseline. The baseline data for the modified intention-to-treat population are shown in Table S3.

A comparison between the patients in the modified intention-to-treat population and those without a confirmed diagnosis of Covid-19 (161 patients) is shown in Table S4. Patients without a confirmed diagnosis of Covid-19 had a higher prevalence of chronic pulmonary obstructive disease or smoking, a lower prevalence of diabetes, and were less frequently receiving supplemental oxygen than patients who had a confirmed diagnosis. Details concerning adherence to the trial regimen and the use of other medications are presented in Tables S5 and S6, respectively.

PRIMARY OUTCOME

Table 2.Primary and Secondary Outcomes (Modified Intention-to-Treat Population).Figure 1.Status of Patients on Day 15.

The primary outcome (status on the seven-point ordinal scale at day 15) was assessed in all patients who were still in the hospital on day 15 exactly and in outpatients (by means of telephone interview) as close to day 15 as possible (see the Supplementary Appendixand Fig. S2).

Among patients with confirmed Covid-19, there were no significant between-group differences in the proportional odds of having a higher (worse) score on the seven-point ordinal scale at 15 days (hydroxychloroquine plus azithromycin vs. control: odds ratio, 0.99; 95% confidence interval [CI], 0.57 to 1.73; P=1.00; hydroxychloroquine alone vs. control: odds ratio, 1.21; 95% CI, 0.69 to 2.11; P=1.00; and hydroxychloroquine plus azithromycin vs. hydroxychloroquine alone: odds ratio, 0.82; 95% CI, 0.47 to 1.43; P=1.00) (Table 2). The distribution of patients’ scores on the seven-level ordinal scale at 15 days is shown in Figure 1.

Figure 2.Distribution of the Ordinal-Scale Results over Time.

The estimates and standard errors for the mixed-model analysis of the primary outcome are shown in Table S7. The distribution of patients in the ordinal-scale categories over time is shown in Figure 2. In this figure, levels 1 and 2 of the seven-level scale are combined (equivalent to the six-level scale previously described) because data on activity limitation were not available on a daily basis for outpatients.

In the intention-to-treat analysis, there was also no significant effect of treatment with either hydroxychloroquine plus azithromycin or hydroxychloroquine alone as compared with the control group (Table S8). Other sensitivity analyses showed similar results (Table S9). The results for the primary outcome were not different across the three prespecified subgroups (Table S10).

SECONDARY OUTCOMES

There were no significant differences in any of the secondary outcomes (Table 2). A total of 43 patients received mechanical ventilation during the first 15 days (11.0% of the patients assigned to receive hydroxychloroquine plus azithromycin, 7.5% of those in the hydroxychloroquine-alone group, and 6.9% of those in the control group). The mean (±SD) numbers of days alive and free from respiratory support were 11.1±4.9 in the group assigned to receive hydroxychloroquine plus azithromycin, 11.2±4.9 in the hydroxychloroquine-alone group, and 11.1±4.9 in the control group.

A total of 18 patients died in the hospital during the trial (5 patients assigned to receive hydroxychloroquine plus azithromycin, 7 in the hydroxychloroquine-alone group, and 6 in the control group). There were no significant between-group differences with regard to the secondary outcomes of thromboembolic complications or acute kidney injury within 15 days, either in the prespecified analyses (Table 2) or in post hoc analyses that accounted for the competing risk of death (Table S11). Marginal estimates of effects for the primary and secondary outcomes are shown in Table S12.

SAFETY

Table 3.Adverse Events (Safety Population).

Adverse events in the safety population are reported in Table 3. More adverse events were reported in patients who received hydroxychloroquine plus azithromycin (39.3%) or hydroxychloroquine alone (33.7%) than in those who received azithromycin alone (18.0%) or none of the trial drugs (22.6%).

Serious adverse events occurred in nine patients (Table 3). Prolongation of the QTc interval was more common in patients receiving hydroxychloroquine plus azithromycin or hydroxychloroquine alone than in patients in the control group; however, fewer patients in the control group had serial electrocardiographic studies performed during follow-up than did patients in the other two groups.

Elevation in liver-enzyme levels was more common in patients receiving hydroxychloroquine plus azithromycin than in the control group. Adverse events in the intention-to-treat population and in the modified intention-to-treat population are shown in Tables S13 and S14, respectively.

In this open-label, multicenter, randomized, controlled trial involving hospitalized patients with confirmed mild-to-moderate Covid-19, a 7-day course of hydroxychloroquine either with azithromycin or alone did not result in better clinical outcomes as measured by a seven-level ordinal scale at 15 days. There was also no effect on any of the secondary outcomes. Occurrence of any adverse event, elevation of liver-enzyme levels, and prolongation of the QTc interval was more frequent in patients receiving hydroxychloroquine with azithromycin or hydroxychloroquine alone than in those receiving neither agent.

The prescription of short courses (<28 days) of hydroxychloroquine or chloroquine in the United States increased almost 2000% between March 21, 2019, and March 21, 2020, with a subsequent decrease.¹⁶ In Brazil, hydroxychloroquine has been formally recommended for the treatment of Covid-19 by the Ministry of Health since March 25, 2020, for severe cases and since May 20, 2020, for mild cases.^5,6

However, no clinical benefit has been observed to date in randomized, controlled trials evaluating hydroxychloroquine for the treatment of Covid-19.^9-11 In addition, higher doses of chloroquine (600 mg twice daily for 10 days) were possibly associated with higher mortality.¹⁷

Our trial enrolled patients with mild-to-moderate Covid-19 who were receiving no more than 4 liters per minute of supplemental oxygen. Hydroxychloroquine was administered relatively early after symptom onset (median, 7 days), which is earlier than the median time from symptom onset to treatment in a trial of remdesivir treatment for Covid-19.¹⁸Furthermore, the addition of azithromycin did not improve outcomes as had been suggested by observational case series.⁴

Our trial has several limitations. First, although the point estimate of effect suggests no major difference between the groups with respect to the primary outcome, the trial cannot definitively rule out either a substantial benefit of the trial drugs or a substantial harm. For the comparison between hydroxychloroquine and control, for example, our data are compatible with odds ratios as low as 0.69 and as high as 2.11.

Second, the trial was not blinded. Third, despite intense efforts to maintain adherence to the assigned treatments, a lack of medications that were perceived as beneficial by clinicians and patients led to some protocol deviations. Fourth, the use of hydroxychloroquine plus azithromycin was widespread among patients hospitalized with Covid-19 in participating hospitals.

The enrollment of patients with no previous use of these medications was challenging, so we decided to enroll patients provided that their previous use since the onset of symptoms was limited to 24 hours.

Finally, although the median time from symptom onset to randomization was 7 days, we included patients up to 14 days after the beginning of symptoms; it is conceivable that interventions that may limit viral replication (e.g., hydroxychloroquine) may be more effective earlier in the course of the disease.

In this trial involving hospitalized patients with mild-to-moderate Covid-19, we did not find a significant difference in a 15-day ordinal clinical-status outcome among groups that received standard care, hydroxychloroquine alone, or hydroxychloroquine plus azithromycin. Patients who received hydroxychloroquine, either with azithromycin or alone, had more frequent events of QTc interval prolongation and elevation of liver-enzyme levels than patients who did not receive either agent.