Assessing the Safety of Direct-Acting Antiviral Agents for Hepatitis C
Abstract
Key Points
Question
Are patients with hepatitis C who receive direct-acting antivirals at increased risk for adverse events compared with those who do not receive these agents?
Findings
In this cohort study of 33 808 patients in 3 health systems, direct-acting antiviral exposure was associated with lower odds of experiencing the following adverse events: death, multiple organ failure, hepatic decompensation, acute-on-chronic liver event, and arrhythmia.
Meaning
Concerns about safety risks based on analyses of the US Food and Drug Administration’s Adverse Events Reporting System did not appear to be confirmed, suggesting that dispensed direct-acting antivirals may be safe for patients with hepatitis C.
Importance
Recent reports based on the US Food and Drug Administration’s voluntary Adverse Events Reporting System raised questions about the safety of direct-acting antivirals (DAAs) for treatment of the hepatitis C virus (HCV).
Objective
To assess the rates of adverse events in patients with HCV infection exposed to DAAs compared with those not exposed.
Design, Setting, and Participants
A retrospective cohort study calculated unadjusted adverse event rates for exposed vs unexposed time, using claims and clinical data from 3 health systems between January 1, 2012, and December 31, 2017. Of 82 419 eligible adults, a total of 33 808 who met eligibility criteria (age, 18-88 years; HCV quantitative result or genotype from 2012 or later; continuously enrolled; naive to DAA treatment at baseline) were included. Marginal structural modeling methods were used to adjust time-to-event analyses for characteristics that are associated with both outcomes and probability of treatment.
Interventions or Exposures
Exposure to DAAs compared with no DAA exposure.
Main Outcomes and Measures
Death, multiple organ failure, liver cancer, hepatic decompensation, acute-on-chronic liver event, acute myocardial infarction, ischemic or hemorrhagic stroke, arrhythmia, acute kidney failure, nonliver cancer, hepatitis B reactivation, hospitalizations, and emergency department visits.
Results
Of the 33 808 patients who met all inclusion criteria, 20 899 (61.8%) were men; mean (SD) age was 57.2 (10.6) years. In unadjusted analyses, DAA exposure was associated with significantly lower rates of death (10.7 vs 33.7 events per 1000 person-years; rate ratio [RR], 0.32, 95% CI, 0.25-0.40). Seven other unadjusted adverse clinical events ratios were below 70% and statistically significant favoring the DAA group: multiple organ failure (RR, 0.56; 95% CI, 0.44-0.72), liver cancer (RR, 0.62; 95% CI, 0.48-0.80), hepatic decompensation (RR, 0.62; 95% CI, 0.52-0.73), acute-on-chronic liver event (RR, 0.68; 95% CI, 0.56-0.84), acute myocardial infarction (RR, 0.64; 95% CI, 0.42-0.97), ischemic stroke (RR, 0.63; 95% CI, 0.42-0.95), and hemorrhagic stroke (RR, 0.47; 95% CI, 0.25-0.89); none favored the non-DAA group. In the marginal structural modeling–adjusted analysis, DAA exposure was associated with statistically significant lower odds of adverse events than non-DAA exposure for death (adjusted odds ratio [aOR], 0.42; 95% CI, 0.30-0.59), multiple organ failure (aOR, 0.67; 95% CI, 0.49-0.90), hepatic decompensation (aOR, 0.61; 95% CI, 0.49-0.76), acute-on-chronic liver event (aOR, 0.71; 95% CI, 0.56-0.91), and arrhythmia (aOR, 0.47; 95% CI, 0.25-0.88).
Conclusions and Relevance
Direct-acting antiviral exposure may not be associated with higher rates of any serious adverse events, including those related to liver, kidney, and cardiovascular systems. Safety concerns based on previous reports did not appear to be supported in this study with more comprehensive data and rigorous statistical methods.
Introduction
Approximately 2.4 million US individuals are currently infected with the hepatitis C virus (HCV)1 and 28% of those with chronic HCV have cirrhosis.2 Annually 1% to 4% of individuals with cirrhosis will develop liver cancer.3 Antiviral treatments for HCV previously required a combination of agents taken over 24 to 48 weeks, were associated with significant adverse effects, and were effective in 54% to 63% of patients who completed treatment.4,5,6 Lower rates of effectiveness were reported in urban patients in minority racial/ethnic groups.7 Thus, the advent of newer direct-acting antivirals (DAAs) that could be administered over 8 to 12 weeks with few significant adverse effects8,9 and sustained virologic response of 93% to 99% across different target populations and treatment regimens10,11,12 was considered a substantial breakthrough in treating HCV.13
Enthusiasm for DAAs was somewhat tempered by a boxed warning issued in October 2016 by the US Food and Drug Administration (FDA) about the potential for reactivation of the hepatitis B virus (HBV) among coinfected individuals.14 This finding prompted the Institute for Safe Medication Practices to analyze the FDA’s Adverse Events Reporting System. They reported 500 cases of liver failure and 1000 cases of severe liver injury among patients taking DAAs over 12 months ending June 30, 2016.15 The authors acknowledged some of the limitations of using the Adverse Events Reporting System data including the voluntary nature of the reporting, lack of detailed patient medical history data, and the possibility of some misclassification because the adverse events of interest are also significant complications of the disease. However, the authors recommended further investigation because of the large number of cases and that approximately 90% of reports were from health professionals.
Postmarketing surveillance is frequently required by the FDA as a condition of approval, particularly among new drugs that have progressed quickly through the approval process. To enable more rapid surveillance, in 2008, the FDA pioneered the use of real-world evidence through the Sentinel Initiative,16 which complements the Adverse Events Reporting System by enabling more in-depth investigation of safety concerns that emerge through voluntary reporting. The Sentinel Initiative uses a common data model that harmonizes data on nearly 200 million people receiving care in about 18 health systems. More recently, the Patient-Centered Outcomes Research Institute created the National Patient-Centered Clinical Research Network (PCORnet) to advance the use of real-world evidence for patient-centered studies including both comparative effectiveness and safety research.17 PCORnet is a large, highly representative, national network of networks with a Sentinel Initiative–based common data model. We used rigorous statistical methods on the rich longitudinal data from 3 PCORnet systems to examine whether patients with HCV who were dispensed newer DAAs experienced higher rates of adverse events than patients with HCV who were not dispensed DAAs.
Methods
Study Design
We conducted a retrospective cohort study using administrative, longitudinal electronic health record and other data collected during the normal course of patient care from January 1, 2012, to December 31, 2017, in 3 health systems. All participants contribute person-time in the untreated (no DAA) group until they fill a prescription for a DAA at which time they contribute person-time to the DAA group until they experience the adverse event of interest or are censored (leave the health system, end of the observation or study period). The study was approved by the Kaiser Permanente Southern California Institutional Review Board and the OneFlorida Institutional Review Board; the Kaiser Permanente Northern California Institutional Review Board ceded to the Southern California Institutional Review Board. The need for patient informed consent was waived by all institutional review boards. Each site conducted its own analyses so the identified data did not leave the study site. The study followed the Strengthening the Reporting of Observational Studies in Epidemiology (STROBE) reporting guideline for reporting observational studies.18
Study Data and Setting
The study was conducted in 3 health systems: Kaiser Permanente Southern California, which serves about 4.5 million members at 15 hospital-based medical centers and 231 medical offices; Kaiser Permanente Northern California, which serves about 4.3 million members at 21 hospital-based medical centers and 247 medical offices; and OneFlorida, whose partners provide health care to more than 10 million Floridians in 22 hospitals and 1240 practice or clinic settings. The systems have complete data capture for the patients included in the study. Data sources included enrollment files, encounters across all settings, diagnoses associated with encounters, laboratory studies and results, and pharmacy dispensing. Diagnoses were coded according to the International Classification of Diseases, 9th Revision, Clinical Modification,19 and International Classification of Diseases, Tenth Revision, Clinical Modification (ICD-10-CM).20
Participants
Using clinical and enrollment data from each system, we identified all adults aged 18 to 88 years who had any indication of an HCV diagnosis (genotype, quantitative or qualitative HCV viral laboratory result, HCV antibody result, ICD code, or medication) and who received care anytime between 2012 and 2017. We further required that patients have an HCV RNA quantitative result or genotype indicating active virus after January 1, 2012; be continuously enrolled 1 year before the index date; and be naive to DAA treatment at study entry (Figure 1).
Flow of Steps to Determine Study Eligibility
DAA indicates direct-acting antiviral; HCV, hepatitis C virus.
Exposure and Outcomes
Exposure was calculated as person-time in the non-DAA and/or DAA group. Entry to the DAA group was triggered on the date patients were dispensed their first prescription for a DAA. The outcomes of interest were serious adverse events: death, multiple organ failure, liver cancer, hepatic decompensation, acute-on-chronic liver event, acute myocardial infarction (AMI), ischemic or hemorrhagic stroke, arrhythmia, acute kidney failure, nonliver cancer, and HBV reactivation. We also examined hospitalizations and emergency department visits. Outcome and covariate definitions are provided in eTable 1 in the Supplement.
We included the outcomes of interest that are most commonly evaluated by the FDA, including liver-related events, and those recommended by 2 of us (A.K.S., D.R.N.). Outcomes were assessed from November 1, 2013, (the first month in which a DAA could have been prescribed) through December 31, 2017. Patients were followed up for up to 180 days after DAA dispensing to restrict the analysis to a time in which adverse events were most likely to be attributable to exposure to a DAA.
For AMI, ischemic stroke, hemorrhagic stroke, multiple organ failure, and arrhythmia, we required the incident appearance of ICD codes to be in an inpatient setting. Codes for acute kidney failure and cancers were identified from either inpatient or outpatient settings.
We constructed hepatic decompensation as a composite variable using the first occurrence of any component: variceal hemorrhage, jaundice, ascites, or hepatic encephalopathy. Because ICD-9-CM codes for hepatic encephalopathy are unreliable and there is no ICD-10-CM code, we used the first dispensed date for rifaximin or lactulose as a proxy.
Acute-on-chronic liver events were defined based on the model for end-stage liver disease (MELD) score. Among patients with cirrhosis, we calculated the following formula: MELD = 3.78 × logbilirubin + 11.2 × loginternational normalized ratio + 9.57 × logcreatinine + 6.43 with the constraint that laboratory values less than 1 were set equal to 1.21 This procedure resulted in a minimum MELD score of 6.43 (higher MELD scores indicate higher levels of severity). Among patients with a MELD score less than 15, we used a 5-point increase in MELD score as a proxy for an acute-on-chronic liver event associated with increased mortality and morbidity.22 To rule out acute spikes in the MELD score due to transient conditions, such as infection, we required the MELD score change to persist for at least 90 days. We also deemed the change in the MELD score to have persisted if there was a liver transplant or death within 90 days following the initial 5-point increase.
We identified HBV reactivations using 3 methods in patients with23,24: (1) a history of positive hepatitis B core antibody and negative hepatitis B surface antigen at the time of initiating DAA therapy who became hepatitis B surface antigen–positive within 180 days after receiving a DAA; (2) undetectable levels of HBV DNA at the time of initiating DAA therapy who had a numeric result within 180 days after receiving a DAA; and (3) a numeric hepatitis B surface antigen result at the time of initiating DAA therapy whose viral load increased by a factor of 10 within 180 days after receiving a DAA. We further required that the reactivations be clinically significant: bilirubin level at least 3 mg/dL (to convert to micromoles per liter, multiply by 17.104), aspartate aminotransferase level at least 400 U/L, or alanine aminotransferase level at least 500 U/L (to convert aspartate aminotransferase and alanine aminotransferase to microkatals per liter, multiply by 0.0167).25
Covariates
We included several covariates in our analysis: demographics (age, sex, race, and ethnicity), year, body mass index, smoking status, history of use (skilled nursing, home health, emergency department, inpatient), laboratory results (MELD score and aspartate aminotransferase, alanine aminotransferase, hemoglobin A1c, and albumin levels), and a calculated aspartate aminotransferase level to platelet ratio index score.26 We defined comorbidities using algorithms of Quan et al.27
We examined patterns of missing data for laboratory tests. The proportion of patients missing laboratory tests ranged from 0.5% for alanine aminotransferase levels to 29.2% for hemoglobin A1c levels. We found no significant differences between the DAA and non-DAA groups in the rates at which these tests were missing. Missing data for laboratory values were imputed with the mean value at baseline. Missing data for other variables were rare and addressed through categorical assignment (race, ethnicity, and smoking status) or mean imputation (body mass index).
Statistical Analysis
We calculated unadjusted adverse event rates by counting the number of individuals who experienced the event and dividing by the total exposure time among all eligible individuals. For each event, the follow-up time for each person ended when 1 of the following occurred: adverse event of interest, death, loss of membership or follow-up, or 180 days after a DAA was dispensed, whichever came first. Separate models of adverse event rates were estimated for each of the 3 systems and for each outcome. Patients were excluded if they had the adverse event of interest before their index date.
Marginal structural models (MSMs) were used to adjust time-to-event analyses for patient characteristics that may affect outcomes, probability of treatment, and probability of censoring.28 The MSM is like the pooled logistic regression approach to survival analysis, but29 MSMs have the added feature that the probability of a patient receiving the treatment is modeled to make the treated and untreated populations more comparable. The MSM adjusts for time-dependent covariates and time-dependent exposures using inverse-of-probability-of-treatment weights. This adjustment may be thought of as the generalization of propensity score inverse-of-probability-of-treatment weights to repeated treatment decisions over time. The MSM adjusts for selection bias due to censoring by loss to follow-up using inverse-of-probability-of-censoring weights. Results using standard methods (eg, Cox proportional hazards regression model with time-varying covariates) may be biased.29
The MSM weights in the outcome models use the estimated probabilities of treatment and censoring from logistic regressions that include both static and time-dependent covariates. Time-varying covariates, such as laboratory values and diagnoses, were updated only until DAA dispensing to prevent biasing treatment outcomes. The approach is an intent-to-treat model with patients staying in the treatment arm until the end of follow-up or censoring. The MSM outcome models include a subset of covariates used in the probability of treatment model (baseline values of age, MELD score, and cirrhosis) to gain some additional robustness from case-mix adjustment while avoiding numeric instability from low adverse event rates. A more detailed description of the method is in the eMethods in the Supplement. To assess the balance produced by the weights, we calculated weighted means for each covariate across untreated points and compared with the weighted mean across treated points (eTable 2 in the Supplement). We also assessed rates of hospitalization and emergency department visits as a more sensitive indicator of potential serious adverse events using Poisson regression with time-varying covariates.
All analyses were stratified by health system. Means and 95% CIs for rate ratios (RRs) were exponentiated from normal approximation intervals in the logarithmic scale. Similarly, logit scale coefficient estimates and their 95% CIs from the MSMs were exponentiated to the odds scale. Estimates from the 3 health systems were combined using random-effects modeling—a common combination technique in meta-analyses.30 In addition to combined estimates and their SEs, the method provided a heterogeneity estimate and test to inform the comparability of the estimates across systems. Tests of homogeneity were conducted at the 5% level.
We assessed the sensitivity of our results to the method of imputing missing laboratory data. The MSM method uses a simple, mean-based imputation method. We tested whether more advanced methods would affect the results. We assumed multivariate normality for the data and used the expectation-maximization algorithm to estimate the parameters and the Monte Carlo Markov chain method to impute. Several of the variables were skewed; therefore, we log-transformed variables before imputing and then back-transformed to the original scale. Because our results were not sensitive to imputation methods, we used the standard MSM approach. Findings were considered significant at P < .05, with 2-tailed testing. Analyses were conducted with SAS, version 9.4 (SAS Institute Inc) and Harvard MSM, macro version 2.24.2015.
Results
As shown in Figure 1, 82 419 patients were eligible for the study and 33 808 met all inclusion criteria. Requiring a quantitative HCV RNA result or genotype had the largest association with eligibility (33 622 [41% reduction]). Table 1 displays patient characteristics by health system and treatment status at study entry. The mean (SD) age was 57.2 (10.6) years (range, 51.7 [12.6] to 58.4 [9.0]) years. Participants were more likely to be men (20 899 [61.8%]; range, 55.2%-64.5%), white (18 562 [54.9%]; range, 49.7%-64.8%), non-Hispanic (27 367 [80.9%]; range, 70.5%-97.4%), and overweight (mean [SD] body mass index, 28.2 (66.6); range, 27.0-28.6 [calculated as weight in kilograms divided by height in meters squared]). Few patients had been previously diagnosed with liver cancer (862 [2.5%]; range, 1.7%-7.3%) or cirrhosis (5313 [15.7%]; range, 13.4%-34.0%) or had received a liver transplant (661 [2.0%]; range, 1.3%-5.7%); 10 952 (32.4%; range, 28.1%-40.9%) had 3 or more comorbid conditions. The proportion of patients dispensed DAAs during the study varied (7796 of 15 074 [51.7%] in health system 1, 6649 of 13 932 [47.7%] in health system 2, and 1079 of 4802 [22.5%] in health system 3). These percentages are within the health systems—not the overall distribution of participants by system. Total person-years of exposure were 7207.2 in the DAA group and 64 823.5 in the non-DAA group.
| Characteristic | No. (%) | |||||
|---|---|---|---|---|---|---|
| Health System 1 | Health System 2 | Health System 3 | ||||
| DAA | No DAA | DAA | No DAA | DAA | No DAA | |
| No. of participants contributing ≥1 d to exposure time | 7796 | 7278 | 6649 | 7283 | 1079 | 3723 |
| Age, y | ||||||
| Mean (SD) | 58.4 (9.0) | 58.0 (10.6) | 57.8 (9.9) | 57.2 (11.9) | 55.8 (10.1) | 51.7 (12.6) |
| 18-44 | 553 (7.1) | 698 (9.6) | 631 (9.5) | 957 (13.1) | 139 (12.2) | 1016 (25.9) |
| 45-64 | 5622 (72.1) | 5000 (68.7) | 4612 (69.4) | 4625 (63.5) | 841 (74.1) | 2528 (64.3) |
| 65-88 | 1621 (20.8) | 1580 (21.7) | 1406 (21.1) | 1701 (23.4) | 155 (13.7) | 386 (9.8) |
| Sex | ||||||
| Men | 4714 (60.5) | 4551 (62.5) | 4122 (62.0) | 4694 (64.5) | 626 (55.2) | 2192 (55.8) |
| Women | 3082 (39.5) | 2727 (37.5) | 2527 (38.0) | 2589 (35.5) | 509 (44.8) | 1738 (44.2) |
| Race | ||||||
| American Indian or Alaska Native | 59 (0.8) | 80 (1.1) | 51 (0.8) | 32 (0.4) | NRa | NRa |
| Asian or Pacific Islander | 552 (7.1) | 454 (6.2) | 376 (5.7) | 349 (4.8) | 12 (1.1) | 20 (0.5) |
| Black | 1147 (14.7) | 1365 (18.8) | 1225 (18.4) | 1283 (17.6) | 327 (30.3) | 1190 (32.0) |
| White | 4527 (58.1) | 3864 (53.1) | 3449 (51.9) | 3617 (49.7) | 694 (64.3) | 2411 (64.8) |
| Other | 490 (6.3) | 433 (5.9) | 173 (2.6) | 202 (2.8) | 37 (3.4) | 85 (2.3) |
| Unknown | 1021 (13.1) | 1082 (14.9) | 1375 (20.7) | 1800 (24.7) | NRa | 13 (0.3) |
| Hispanic ethnicity | 1169 (15.0) | 1236 (17.0) | 1738 (26.1) | 2146 (29.5) | 51 (4.4) | 101 (2.6) |
| BMI, mean (SD) | 28.4 (5.7) | 28.2 (5.9) | 28.6 (5.6) | 28.3 (5.9) | 28.4 (6.4) | 27.0 (6.2) |
| History of smoking | 4782 (61.3) | 4677 (64.3) | 4343 (65.3) | 5060 (69.5) | 764 (70.8) | 2833 (76.1) |
| Liver-related diagnoses at study entry | ||||||
| Liver cancer | 136 (1.7) | 196 (2.7) | 139 (2.1) | 166 (2.3) | 79 (7.3) | 146 (3.9) |
| Liver transplant | 117 (1.5) | 95 (1.3) | 191 (2.9) | 109 (1.5) | 62 (5.7) | 87 (2.3) |
| Cirrhosis | 1042 (13.4) | 995 (13.7) | 1079 (16.2) | 1117 (15.3) | 367 (34.0) | 713 (19.2) |
| Decompensated cirrhosis, % of cirrhotic | 339 (32.5) | 435 (43.7) | 377 (34.9) | 446 (39.9) | 139 (37.9) | 366 (51.3) |
| Ascites, % of cirrhotic | 221 (21.2) | 313 (31.5) | 245 (22.7) | 310 (27.8) | 102 (27.8) | 268 (37.6) |
| Hemorrhagic varices, % of cirrhotic | 78 (7.5) | 92 (9.2) | 114 (10.6) | 112 (10.0) | 20 (5.4) | 62 (8.7) |
| Encephalopathy drug dispensed (lactulose, rifaximin), % of cirrhotic | 224 (21.5) | 276 (27.7) | 213 (19.7) | 263 (23.5) | 111 (30.2) | 264 (37.0) |
| Laboratory values at study entry | ||||||
| MELD score in patients with cirrhosisb | ||||||
| <10 | 743 (71.3) | 539 (54.2) | 676 (62.7) | 555 (49.7) | 237 (64.6) | 399 (56.0) |
| 10-15 | 241 (23.1) | 284 (28.5) | 309 (28.6) | 345 (30.9) | 86 (23.4) | 191 (26.8) |
| >15 | 58 (5.6) | 172 (17.3) | 94 (8.7) | 217 (19.4) | 44 (12) | 123 (17.3) |
| Albumin <3.5 g/dL | 479 (7.3) | 909 (15.7) | 912 (17.3) | 1401 (25.2) | 162 (15.9) | 906 (26.2) |
| Platelets <90 000 × 103/μL | 468 (6.1) | 521 (7.3) | 513 (7.8) | 673 (9.4) | 126 (12.3) | 340 (9.6) |
| Charlson Comorbidity Index | ||||||
| Charlson score, mean (SD) | 2.8 (2.7) | 3.2 (3.2) | 2.6 (2.6) | 2.9 (2.9) | 3.7 (3.2) | 3.4 (3.4) |
| No. of comorbidities | ||||||
| 0 | 760 (9.7) | 742 (10.2) | 684 (10.3) | 771 (10.6) | 71 (6.6) | 566 (15.2) |
| 1 | 2562 (32.9) | 2194 (30.1) | 2479 (37.3) | 2608 (35.8) | 296 (27.4) | 997 (26.8) |
| 2 | 2109 (27.1) | 1735 (23.8) | 1617 (24.3) | 1635 (22.4) | 271 (25.1) | 759 (20.4) |
| ≥3 | 2365 (30.3) | 2607 (35.8) | 1869 (28.1) | 2269 (31.2) | 441 (40.9) | 1401 (37.6) |
Abbreviations: BMI, body mass index (calculated as weight in kilograms divided by height in meters squared); DAA, direct-acting antiviral; MELD, model for end-stage liver disease; NR, not reported.
SI conversion factors: To convert albumin to grams per liter, multiply by 10; platelets to ×109 per liter, multiply by 1.
aCounts 10 or lower.
bHigher MELD scores indicate higher levels of severity.
The unadjusted rate of observed events per 1000 persons per year during exposed and unexposed time is reported in Table 2. Being in the DAA group was associated with significantly lower death rates (10.7 vs 33.7 events per 1000 person-years; RR, 0.32; 95% CI, 0.25-0.40). Seven of the other adverse clinical event RRs were significant and below 70%, favoring the DAA group: multiple organ failure (RR, 0.56; 95% CI, 0.44-0.72), liver cancer (RR, 0.62; 95% CI, 0.48-0.80), hepatic decompensation (RR, 0.62; 95% CI, 0.52-0.73), acute-on-chronic liver event (RR, 0.68; 95% CI, 0.56-0.84), AMI (RR, 0.64; 95% CI, 0.42-0.97), ischemic stroke (RR, 0.63; 95% CI, 0.42-0.95), and hemorrhagic stroke (RR, 0.47; 95% CI, 0.25-0.89). Being in the DAA group was associated with significantly lower rates of hospitalization (RR, 0.50; 95% CI, 0.48-0.52) and emergency department visits (RR, 0.65; 95% CI, 0.63-0.66). None of the unadjusted comparisons favored the non-DAA group. The size of the eligible population for HBV reactivation varied by method from 2308 for the first method (most sensitive) to 54 for the third method (most specific) and we observed only 1 clinically significant event.
| Event | No.a | Health System 1 | No.a | Health System 2 | No.a | Health System 3 | No.a | Combined | Rate Ratio (95% CI) | ||||
|---|---|---|---|---|---|---|---|---|---|---|---|---|---|
| Events, No. | Rate/1000 PY | Events, No. | Rate/1000 PY | Events, No. | Rate/1000 PY | Events, No. | Rate/1000 PY (95% CI) | ||||||
| Death | 0.32 (0.25-0.40) | ||||||||||||
| DAA | 7796 | 32 | 8.8 | 6649 | 32 | 10.2 | 1079 | 13 | 28.3 | 15 524 | 77 | 10.7 (8.3-13.1) | |
| No DAAb | 15 074 | 750 | 26.6 | 13 932 | 1033 | 37.3 | 4802 | 403 | 44.9 | 33 808 | 2186 | 33.7 (32.3-35.1) | |
| Multiple organ failure | 0.56 (0.44-0.72) | ||||||||||||
| DAA | 7604 | 33 | 9.4 | 6491 | 28 | 9.2 | 1012 | 0c | 15.9 | 15 107 | 68 | 9.7 (7.4-12.0) | |
| No DAA | 14 673 | 428 | 15.7 | 13 611 | 465 | 17.3 | 4586 | 185 | 21.8 | 32 870 | 1078 | 17.2 (16.2-18.3) | |
| Liver cancer | 0.62 (0.48-0.80) | ||||||||||||
| DAA | 7552 | 30 | 8.6 | 6404 | 23 | 7.6 | 949 | 11 | 26.8 | 14 905 | 64 | 9.3 (7.0-11.5) | |
| No DAA | 14 726 | 380 | 13.9 | 13 596 | 423 | 15.8 | 4572 | 128 | 15.2 | 32 894 | 931 | 14.9 (13.9-15.8) | |
| Hepatic decompensation | 0.62 (0.52-0.73) | ||||||||||||
| DAA | 6923 | 67 | 20.9 | 5786 | 60 | 22.1 | 787 | 22 | 65.3 | 13 496 | 149 | 23.8 (20-27.7) | |
| No DAA | 13 543 | 797 | 32.3 | 12 518 | 921 | 38.1 | 3900 | 430 | 63.4 | 29 961 | 2148 | 38.6 (37-40.2) | |
| Acute-on-chronic liver event | 0.68 (0.56-0.84) | ||||||||||||
| DAA | 7023 | 48 | 14.8 | 5606 | 44 | 16.7 | 692 | 10 | 33.8 | 13 321 | 102 | 16.5 (13.3-19.7) | |
| No DAA | 12 861 | 474 | 21.0 | 11 373 | 551 | 25.0 | 2803 | 169 | 35.1 | 27 037 | 1194 | 24.1 (22.8-25.5) | |
| Acute myocardial infarction | 0.64 (0.42-0.97) | ||||||||||||
| DAA | 7510 | 12 | 3.4 | 6438 | 11 | 3.6 | 1011 | NRc | 0.0 | 14 959 | 23 | 3.3 (2-4.7) | |
| No DAA | 14 433 | 125 | 4.7 | 13 430 | 136 | 5.1 | 4517 | 61 | 7.2 | 32 380 | 322 | 5.2 (4.6-5.8) | |
| Ischemic stroke | 0.63 (0.42-0.95) | ||||||||||||
| DAA | 7385 | 16 | 4.7 | 6396 | NRc | 2.0 | 977 | NRc | 7.0 | 14 758 | 25 | 3.6 (2.2-5.1) | |
| No DAA | 14 166 | 183 | 6.9 | 13 366 | 104 | 3.9 | 4368 | 64 | 7.9 | 31 900 | 351 | 5.8 (5.1-6.4) | |
| Hemorrhagic stroke | 0.47 (0.25-0.89) | ||||||||||||
| DAA | 7406 | NRc | 1.5 | 6414 | NRc | 1.7 | 982 | 0 | 0.0 | 14 802 | 10 | 1.5 (0.6-2.3) | |
| No DAA | 14 166 | 64 | 2.4 | 13 366 | 78 | 2.9 | 4368 | 47 | 5.8 | 31 900 | 190 | 3.1 (2.6-3.5) | |
| Arrhythmia | 0.68 (0.43-1.07) | ||||||||||||
| DAA | 6757 | 11 | 3.5 | 5865 | NRc | 1.8 | 774 | NRc | 11.4 | 13 396 | 19 | 3.2 (1.8-4.5) | |
| No DAA | 12 999 | 96 | 3.9 | 12 302 | 116 | 4.7 | 3367 | 47 | 7.1 | 28 668 | 230 | 4.7 (4.1-5.2) | |
| Acute kidney failure | 0.72 (0.61-0.84) | ||||||||||||
| DAA | 7304 | 73 | 21.6 | 6123 | 64 | 22.3 | 894 | 24 | 62.3 | 14 321 | 161 | 24.2 (20.5-28.0) | |
| No DAA | 14 134 | 702 | 27.3 | 13 002 | 866 | 34.3 | 4111 | 397 | 54.4 | 31 247 | 1965 | 33.7 (32.2-35.2) | |
| Cancer (nonliver) | 0.78 (0.65-0.94) | ||||||||||||
| DAA | 6575 | 53 | 17.4 | 5790 | 59 | 21.7 | 889 | 15 | 39.1 | 13 254 | 127 | 20.7 (17.1-24.3) | |
| No DAA | 13 156 | 614 | 25.6 | 12 522 | 621 | 25.8 | 4265 | 235 | 30.6 | 29 943 | 1470 | 26.4 (25.0-27.7) | |
| Hospitalization | 0.50 (0.48-0.52) | ||||||||||||
| DAA | 7796 | 1974 | 156.9 | 6649 | 1789 | 148.3 | 1079 | 496 | 324.5 | 15 524 | 4259 | 162.8 (157.9-167.7) | |
| No DAAb | 15 074 | 7114 | 252.2 | 13 932 | 7938 | 286.7 | 4802 | 6032 | 672.0 | 33 808 | 21 084 | 325 (320.6-329.4) | |
| ED visit | 0.65 (0.63-0.66) | ||||||||||||
| DAA | 7796 | 7136 | 567.4 | 6649 | 6381 | 529.1 | 1079 | 907 | 593.5 | 15 524 | 14 424 | 551.2 (542.3-560.2) | |
| No DAAb | 15 074 | 23 378 | 828.8 | 13 932 | 21 734 | 785.0 | 4802 | 10 243 | 1141.2 | 33 808 | 55 355 | 853.4 (846.2-860.5) | |
Abbreviations: DAA, direct-acting antiviral; ED, emergency department; NR, not reported; PY, person-years.
aNumber of participants who contributed 1 or more days of exposure to the rate calculations. Participants who were dispensed a DAA contributed exposure time to the no DAA rate calculation before being dispensed a DAA.
bThese counts include 55 patients whose no DAA exposure time ended on the same day they became eligible (18 in site 1, 32 in site 2, and 5 in site 3). Twenty-seven of these patients received a new DAA on the day they became eligible and started contributing DAA exposure time, 25 were censored by receiving an older DAA, and 3 were censored by end of membership. These cases contribute no exposure time and no events to the no DAA rate calculation.
cCounts 10 or lower.
Figure 2 displays the MSM-adjusted combined estimated odds of experiencing an adverse event for patients who received a DAA compared with those who did not receive a DAA. The DAA exposures were associated with statistically significant lower odds of adverse events than non-DAA exposures for death (adjusted odds ratio [aOR], 0.42; 95% CI, 0.30-0.59), multiple organ failure (aOR, 0.67, 95% CI, 0.49-0.90), hepatic decompensation (aOR, 0.61; 95% CI, 0.49-0.76), acute-on-chronic liver event (aOR, 0.71; 95% CI, 0.56-0.91), and arrhythmia (aOR, 0.47; 95% CI, 0.25-0.88). We also observed significantly lower adjusted rates of hospitalizations (adjusted rate ratio [aRR], 0.71; 95% CI, 0.60-0.84) and emergency department visits (aRR, 0.82; 95% CI, 0.77-0.87).
Adjusted Odds of Experiencing Adverse Events Among Those Exposed and Not Exposed to Direct-Acting Antiviral (DAA) Medications
aOR indicates adjusted odds ratio; aRR, adjusted rate ratio.
aFailed test of homogeneity (heterogeneity estimate, 69% for liver cancer and 74% for acute myocardial infarction).
bCalculated as aRRs.
For 2 of the adverse events (liver cancer and AMI), the test for homogeneity indicated significant heterogeneity in results by health system (eTable 3 in the Supplement). The adjusted odds of being diagnosed with liver cancer were significantly lower among those dispensed DAAs in health system 1 (aOR, 0.51; 95% CI, 0.32-0.80) and health system 2 (aOR, 0.44; 95% CI, 0.26-0.74). The aOR in health system 3 was not statistically significant but favored those not dispensed DAAs (aOR, 1.45; 95% CI, 0.65-3.22). No AMIs were observed in health system 3 among those dispensed DAAs; the results in health system 1 favored those not dispensed DAAs but were not significant (aOR, 1.57; 95% CI, 0.84-2.95); the odds of having an AMI in health system 2 were statistically significantly lower among those dispensed DAAs (aOR, 0.41; 95% CI, 0.20-0.83).
Discussion
In this large cohort study conducted in 3 health systems, we found no evidence that DAA exposure was associated with a higher rate of serious adverse events. We examined multiple outcomes, including those related to liver, kidney, and cardiovascular systems, as well as hospitalizations and ED visits, and used rigorous statistical methods to address some of the threats to validity that are common in cohort studies.
This research contributes to the literature on the safety profile of this newer class of medications for treating HCV. No medication is without risks and multiple randomized trials have demonstrated the potential benefits associated with these agents.9 When patients and physicians are considering treatment options for HCV, they must determine whether the potential risks associated with the treatment outweigh the potential benefits. Because clinical trials are commonly conducted with participants who have different demographic and health profiles than patients who are subsequently offered medication therapy, the results of postmarketing studies, such as this one, that are based on real-world patients and their experiences can contribute a richer source of information for shared decision making.31 Our study included a higher proportion of patients from racial and ethnic minorities than in most of the trials to date (14.7%-32.0% black, 0.5%-7.1% Asian or Pacific Islander, 2.6%-29.5% Hispanic). Our study also included patients who are typically excluded from clinical trials, such as those with a previous diagnosis of liver cancer, prior liver transplant, cirrhosis, and multiple comorbidities.
Examining the safety of DAAs presents challenges because some of the outcomes of interest are also known complications of HCV. The underlying disease process can take more than 20 years to progress to clinically significant symptoms and most people with HCV do not develop these complications. It is challenging, particularly for liver-related outcomes, to determine whether the adverse events observed were caused by the medication or were part of the course of the disease. The comparison group that we constructed and our analytic methods are tools to parse these competing explanations in cohort studies. Our findings on liver cancer are consistent with other studies,32 including a recent cohort study in the Veterans Affairs system33 and a meta-analysis.34 Other adverse events, such as cardiovascular and kidney-related events, are more likely to be due to the drug than to the underlying disease. The findings related to emergency department visits and hospitalizations, which were included as a more sensitive indicator of potential adverse events, also favored the DAA group. Because we observed a consistent pattern across different types of adverse events, we have greater confidence that DAAs may not be associated with increased risks of serious adverse events.
The US Preventive Services Task Force35 recommends that persons who are at high risk for acquiring HCV (eg, past or current injection drug use, blood transfusion before 1992, significant direct percutaneous exposures) and those born between 1945 and 1965 be screened for HCV infection. Those who have HCV may consider, in consultation with their health care professional, whether treatment is appropriate. For patients who are otherwise apparently healthy, the decision to use a medication that could cause a health problem can be particularly difficult. The adverse event profile that we observed herein should contribute useful information for those who face this decision. For patients who are already experiencing significant health effects of HCV, this study may provide evidence that DAAs are not associated with higher adverse event rates.
Strengths and Limitations
The consistency in results across 3 large, demographically diverse health systems in 2 different regions of the country is a strength of the study and provides a greater measure of confidence in the conclusions than a single-site study. The health systems have comprehensive clinical data available, which enabled us to control for a variety of demographic and clinical characteristics using rigorous statistical methods. The ability to reasonably rapidly address questions of importance to patients demonstrates the potential for ongoing and robust monitoring of drug safety using real-world data, particularly when the events are rare or might be triggered by other factors, such as comorbidities or other medications, that typically lead to patients being excluded from trials.
Our study also has some limitations. This was a cohort study and is subject to the known biases for such designs. Although we had a rich collection of clinical data available, it is likely that some of our results may be explained by unmeasured confounding by indication. Although there were no formal restrictions on access to treatment in the systems, it is likely that the decision to treat was different in the earliest days of DAA availability. We controlled for year and model the decision to treat to address this possible factor. In this study, confounding by indication or selection bias was complicated by the possibility of competing confounding mechanisms. Our findings are consistent with a bias toward healthier patients receiving DAAs (eg, lower proportion with 2 or more comorbidities among those dispensed DAAs). However, some of the associations are complex. For example, we observed that people with cirrhosis were more likely to be treated with DAAs (consistent with a bias toward sicker patients) but, among those with cirrhosis, MELD scores were lower among the treated patients (consistent with a bias toward healthier individuals). Differences that we observed between the health systems might be explained by different channeling mechanisms at work in each system.
Conclusions
We found no evidence that patients dispensed DAAs experienced higher rates of adverse liver-, cardiovascular-, kidney-, or emergency department visit and hospitalization–related events in 3 health systems. Although it is tempting to conclude that DAAs are protective against many serious adverse outcomes, these outcomes may be a consequence of channeling healthier patients to DAA treatment. A more conservative conclusion is that DAA exposure may not be associated with higher rates of adverse events.
eTable 1. Definitions of Outcome and Covariate Variables Used in the Study
eMethods. Additional Methodologic Details on the Marginal Structural Modeling Method
eTable 2. Differences Between Treated and Untreated Before and After Applying Marginal Structural Modeling Weights
eTable 3. Marginal Structural Modeling Adjusted Odds Ratio (OR) or Rate Ratio (RR) of Adverse Events by Health System and Combined
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