Figures
Abstract
Background
Interferon-based therapy (IBT) has been the standard of care for hepatitis C virus (HCV) infection. However, conflicting results exist regarding the effects of IBT on risk of developing hepatocellular carcinoma (HCC) and cirrhosis-associated complications, and most included highly selected patients.
Methods
This 8-year cohort study was based on the Longitudinal Health Insurance Database 2000 (LHID 2000) consisting of 1,000,000 beneficiaries randomly selected from all Taiwan National Health Insurance enrollees in 2000 (>23.7 million). Patients with newly detected HCV infections (n = 11,264) were classified based on treatment and clinical outcomes. IBTs were defined as regimens that included interferon- alfa, pegylated interferon- alfa -2a, or pegylated interferon- alfa -2b for at least 3 months. The Cox proportional hazards models were used to estimate the hazard ratio (HR) and associated confidence interval (CI) of HCC and cirrhosis-associated complications for IBT.
Results
The 8-year incidence rate for HCC was 3.9% among patients who received IBT and 5.6% among those who did not. The HCC-free survival rate was significantly higher among patients receiving IBT during the 8-year period than their counterpart (adjusted HR, 0.50; 95% CI, 0.31–0.81; P = .004). Similarly, the event-free survival rates for esophageal variceal bleeding (adjusted HR, 0.45; 95% CI, 0.22–0.91; P = .026), hepatic encephalopathy (adjusted HR, 0.38; 95% CI, 0.21–0.69; P = .001), ascites (adjusted HR, 0.28; 95% CI, 0.14–0.57; P<.001), and cirrhosis (adjusted HR, 0.63; 95% CI, 0.44–0.91; P = .013) were significantly higher among patients who received IBT than those who did not, after adjustment for associated factors.
Citation: Hsu C-S, Huang C-J, Kao J-H, Lin HH, Chao Y-C, Fan Y-C, et al. (2013) Interferon-Based Therapy Decreases Risks of Hepatocellular Carcinoma and Complications of Cirrhosis in Chronic Hepatitis C Patients. PLoS ONE 8(7): e70458. https://doi.org/10.1371/journal.pone.0070458
Editor: Michael Alan Polis, National Institute of Allergy and Infectious Diseases, United States of America
Received: October 25, 2012; Accepted: June 21, 2013; Published: July 23, 2013
Copyright: © 2013 Hsu et al. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: This work was supported in part by grants from the Buddhist Tzu Chi General Hospital, Taipei Branch (TCRD-TPE-100-C1-2) and the National Science Council, Executive Yuan, Taiwan (NSC 99-2314-B-303-004 and NSC 99-2628-B-038-013-MY3). The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Competing interests: Ching-Sheng Hsu has received research grants from the Buddhist Tzu Chi General Hospital, Taipei Branch (TCRD-TPE-100-C1-2), the Department of Health, and the National Science Council, Executive Yuan, Taiwan (NSC99-2314-B-303-004). Jia-Horng Kao does consultancy for Abbott, Bristol-Myers Squibb, Gilead Sciences, GlaxoSmithKline, Merck Sharp & Dohme, Novartis, and Roche; on speaker’s bureaus for Abbott, Roche, Bayer, Bristol-Myers Squibb, GlaxoSmithKline, and Novartis. This does not alter the authors’ adherence to all the PLOS ONE policies on sharing data and materials.
Introduction
Hepatitis C virus (HCV) chronically infects approximately 180 million people worldwide and is one of the major causes of liver disease, including hepatitis, cirrhosis, and hepatocellular carcinoma (HCC) [1], [2]. Although interferon-based therapy (IBT) has been the mainstay of HCV treatment for decades [3]–[5], evidence for its long-term effects on clinical outcomes such as HCC and complications of cirrhosis remains elusive [6]–[10]. Some studies demonstrated beneficial effects of interferon (IFN) for chronic hepatitis C (CHC) patients [11]–[16] whereas others failed to show such effects [17]–[19]. In addition, the effects of IBT among non-responders [9], [20], [21] and those with advanced fibrosis or cirrhosis [22] are inconsistent across different studies. Of note, most published reports that demonstrated decreased risks of HCC or complications of cirrhosis in CHC patients receiving IFN treatment were based on highly selected patients, such as patients who received care at tertiary medical centers [15], [16], [18], [19], [22]–[25], had advanced fibrosis or cirrhosis [7], [12], [14], [18], [22], [26], had liver histological data [11], [19], [23], or failed to previous antiviral treatment [9], or were limited by small sample sizes [7], [14], [18], [19], [22], [26], [27]. The question of whether these observations could be extrapolated to all HCV patients remains unanswered; finding answers to this important clinical question requires large-scale studies.
As Taiwan is a hyperendemic area of chronic viral hepatitis [28], HCC and cirrhosis are the leading causes of death in Taiwanese people [29]. Therefore, the Bureau of Taiwan National Health Insurance (NHI) started to reimburse IBT for CHC patients since 2003. In this study, we analyzed the Longitudinal Health Insurance Database 2000 (LHID 2000) that included a nationally representative population, and used an epidemiologic approach to examine the long-term effects of IBT on risks of HCC and complications of cirrhosis. We hypothesized that IBT is associated with decreased risk of HCC and complications of cirrhosis in chronic hepatitis C patients.
Patients and Methods
Ethics Statement
This study was conducted in accordance with the Helsinki Declaration. We used the anonymized LHID2000 data released by Taiwan National Health Research Institutes, which is available to public access for research. Information that could be used to identify patients or care providers, including medical institutions and physicians, was scrambled before being sent to the National Health Research Institutes for database construction and was further scrambled before being released to each researcher. Thus, there is no reasonable basis to believe that the remaining health information could be used to identify a person. All researchers who wish to use the NHIRD and its data subsets are required to sign a written agreement declaring that they have no intention of attempting to obtain information that could potentially violate the privacy of patients or care providers.
Study Design and Data Source
This study used a retrospective cohort study design. The NHI program in Taiwan is a compulsory program providing universal and quality healthcare to the people at affordable costs. It now covers 99.6% of all the population in Taiwan with an age distribution of 15.65% <15 year-old and 10.74% >65 year-old [30]. The LHID 2000 was released by the Taiwan National Health Research Institutes and includes the original claim data and registration files for 1,000,000 individuals randomly sampled from the 2000 Registry for Beneficiaries of the Taiwan NHI program, which maintains the registration data of any individual who was once a beneficiary of NHI program during the period of 1996–2000. There are approximately 23,720,000 individuals in this registry. The Taiwan National Health Research Institutes claimed that there were no statistically significant differences in gender distribution between the randomly sampled beneficiaries in the LHID 2000 and all beneficiaries under the NHI program.
According to the international consensus recommendations on HCC [31], patients with HCV infection are suggested to receive surveillance for HCC by ultrasonography and a-fetoprotein examinations every 6 months in Taiwan. Moreover, CHC patients receiving IBT are scheduled for follow-up visits and medication refills in at least every 4 weeks. Therefore, in this study, we extracted the following variables of all subjects during their surveillance and follow-up, including HCV diagnosis, patient’s age in years, gender, comorbidities [diabetes mellitus, obesity, human immunodeficiency virus (HIV), alcohol intoxication, ischemic heart diseases, cerebrovascular disease, chronic obstructive pulmonary diseases, chronic renal failure, and hepatitis B (Table S1) on the HCV index date], HCC, cirrhosis, hepatic encephalopathy, esophageal varices bleeding, ascites, and the use of IBT.
Study Sample
The study sample for the current study was patients with the first HCV infection diagnosis between January 1, 2000 and December 31, 2007, identified by using the International Classification of Diseases, Ninth Revision, Clinical Modification (ICD-9-CM) codes (Table S1). A total of 12,501 subjects with HCV infection were identified. Subjects with a history of HCV infection before January 1, 2000 (n = 1,237) were excluded, resulting in a total of 11,264 newly detected HCV subjects. Those subjects with unidentified gender (n = 4) were further excluded for the sample used in analyzing each endpoint.
Interferon-based Treated and Non-treated Cohorts
The independent variable of interest was IBT. IBT was identified by drug codes for interferon alfa, pegylated interferon alfa-2a, pegylated interferon alfa-2b with or without ribavirin (Table S2). Because NHI in Taiwan reimbursed CHC patients 4–6 months of interferon or 6 months of pegylated interferon-based treatment during 2000–2008, and most patients who did not achieve early virologic response after 3 months of treatment discontinued IBT [3]–[5], we selected patients receiving ≧3 months of IBT into our analyses, and a cutoff of 6 months to differentiate short and longer-term IBT use. Those patients who maintained IBT for a period of ≧3 months were designated as the treated cohort, and those who received the treatment for a period of <3 months were excluded (n≦55 for analyses of each clinical outcome). The ones who did not receive any IBT between 2000 and 2008 were designated as the control cohort. The treatment cohort was further divided into those who received IBT <6 months and those who received IBT for ≧6 months.
Study Endpoints and Confounders
The endpoint in this study was whether a HCV patient had a new diagnosis of any one of the selected clinical outcomes, including HCC, cirrhosis, hepatic encephalopathy, esophageal varices bleeding, or ascites. All selected clinical outcomes were identified by using ICD-9-CM codes corresponding to the clinical information during the follow-up. For examples, the diagnosis of HCC was based on either histological confirmation or positive image findings [31]. To confirm a new diagnosis of any one of the selected clinical outcomes and avoid misclassifications of patients who had an early HCC or a milder form of a specific type of event outcomes, all patients with a diagnosis of a specific type of event outcomes before the HCV index date and within 6 months after the HCV index date were excluded before analysis for that specific outcome. All enrolled subjects were tracked until the end of 2008 to identify these clinical outcomes. A combined outcome of cirrhosis, “any cirrhosis complication”, was defined as the presence of any one of the cirrhosis-associated complications, including hepatic encephalopathy, esophageal varices bleeding and ascites.
The survival time was defined as the period between the HCV index date of selection and the first date when a specific event outcome was identified. For those who suffered from multiple episodes of a specific event outcome, only the first event of the respective outcome was included.
We extracted baseline variables frequently associated with HCC and cirrhosis relevant complications on the HCV index date and examined their influences on the impact of IBT and the risk of a specific type of outcomes. These baseline prognostic factors included the patient’s age in years, gender, comorbidities [diabetes mellitus, obesity, human immunodeficiency virus (HIV), alcohol intoxication, ischemic heart diseases, cerebrovascular disease, chronic obstructive pulmonary diseases, chronic renal failure, and hepatitis B] (Table S1).
Statistical Analysis
The Statistical Package for the Social Sciences, version 16.0 (SPSS Inc., Chicago, IL, USA) was used to perform the statistical analyses in this study. The Mann–Whitney U-tests and Chi-square tests were used to examine the differences between treated and non-treated groups. The Cox proportional hazards models were used to estimate the association of IBT with outcomes. We estimated the hazard ratio (HR) and associated confidence interval (CI) for each outcome. In consideration the influences of known prognostic factors on the impact of IBT and the risk of a specific type of outcomes, multivariable Cox models were developed to control for possible confounding variables. To examine the effects of different IBT durations on the risk of HCC and cirrhosis-associated complications, the risk of HCC and cirrhosis-associated complications in patients who received <6 months of IBT and patients who received ≧6 months of IBT was compared with that of those who were not treated. Interaction terms for IBT and each of the confounders were included in separate models. The loss to follow-up rate (withdrawing from the NHI Program) was calculated between IBT treated and non-treated groups for all endpoints analyzed. The proportional hazards assumption was tested and was not violated.
We also calculated the number of patients needed to be treated for one additional patient to benefit (number needed to benefit, NNTB) or be harmed (number needed to harm, NNTH) [32].
As the occurrence of cirrhosis might impact the prognosis of HCV patients, we further extracted the number of patients with a diagnosis of cirrhosis before the IBT was initiated, and examined the effect of IBT on outcomes by Cox proportional hazards models and adjusted for cirrhosis occurring after the index day (i.e., between the HCV index date and the identification of outcomes or till the end of 2008 for those without outcomes).
Because the IBT group might receive a closer check-up than the non-IBT group, we further compared the number of ultrasonography and alpha-fetoprotein (AFP) examinations between IBT and non-IBT groups to examine this inherited “detection bias” introduced by the differential surveillance and follow-up between groups. The number of ultrasonography examinations was further adjusted in Cox proportional hazards models testing the effects of IBT on endpoints of interest.
Results
Demographic Data
Between January 1, 2000 and December 31, 2007, 11,264 patients with a newly diagnosis of HCV infection were identified. Finally, 10,058 without a diagnosis of HCC, 10,768 without a diagnosis of esophageal varices bleeding, 10,762 without a diagnosis of hepatic encephalopathy, 10,642 without a diagnosis of ascites, 8,964 without a diagnosis of cirrhosis, and 10,366 without a diagnosis of “any cirrhosis complication” before the HCV index date and within 6 months after the HCV index date were included for analyses of the association of IBT with each clinical outcome. The IBT usage rates between the included and excluded HCV patients were comparable for each clinical outcome, while the loss to follow-up rate (withdrawing from the NHI Program) was significantly higher in the non-IBT treated groups for all endpoints analyzed (hepatocellular carcinoma [Table S3-a], esophageal varices bleeding [Table S3-b], hepatic encephalopathy, [Table S3-c],ascites [Table S3-d], cirrhosis [Table S3-e], and any cirrhosis complication [Table S3-f]; All P<0.001).
The overall person-years of follow-up for different clinical outcomes–HCC, esophageal varices bleeding, hepatic encephalopathy, ascites, cirrhosis, and “any cirrhosis complication” were 48217.4, 52671.4, 52294.0, 51635.9, 41724.7, and 49754.4, respectively. The median duration of follow-up was 4.7, 4.8, 4.7, 4.7, 4.5, and 4.6 years, respectively, for HCC, esophageal varices bleeding, hepatic encephalopathy, ascites, cirrhosis, and “any cirrhosis complication”. The information on the person-years of follow-up for other clinical outcomes stratified by treatment group (i.e., no treatment, <6 months of IBT use, and ≧6 months of IBT use) and the median follow-up duration are provided in Tables S4 and S5. Of those who received IBT, approximately 98.4% received pegylated interferon alfa-2b combined with ribavirin. The median duration of treatment was 6 months (inter-quartile range: 5–6 months). The distributions of selected demographic characters were comparable between the IBT treated and non-treated cohorts, with the exception that the treated cohort was male predominant, younger, and had fewer HBV infection and fewer chronic renal failure than those in the non-treated cohort (Table 1). Moreover, the mean number of ultrasonography and AFP examinations were significantly higher in the IBT group compared with the non-treated group for all endpoints (hepatocellular carcinoma [Table S6-a], esophageal varices bleeding [Table S6-b], hepatic encephalopathy, [Table S6-c], ascites [Table S6-d], cirrhosis [Table S6-e], and any cirrhosis complication [Table S6-f]; All P<0.001).
Impact of IBT on the Risk of HCC, Cirrhosis, Hepatic Encephalopathy, Esophageal Varices Bleeding, and Ascites
The 8-year incidence of HCC for the IBT-treated and non-treated groups was 3.9% and 5.6%, respectively. Among the IBT-treated patients, the incidence of HCC was 3.1% and 4.9%, respectively, for those who received IBT for 6 months and longer and those who received IBT for less than 6 months. The overall incidence of other clinical outcomes and the incidence stratified by treatment group were presented in Table S7. The NNTB for these clinical outcomes were 59 for HCC, 159 for esophageal variceal bleeding, 70 for hepatic encephalopathy, 48 for ascites, 94 for cirrhosis, and 42 for “any cirrhosis complication” (Data not shown, please see Table S8).
Patients in the treated cohort had a higher survival rate for all newly detected clinical outcomes than the ones in non-treated cohort, and the differences were significant for ascites (p = 0.013) and “any cirrhosis complication” (p = 0.016) but not for HCC, cirrhosis, esophageal varices bleeding and hepatic encephalopathy (Unadjusted Model, Table 2).
The percentage of HCV patients with a diagnosis of cirrhosis before the IBT for patients who developed different endpoints–HCC, esophageal varices bleeding, hepatic encephalopathy, ascites and “any cirrhosis complication “ was 22.8%, 27%, 27.4%, 27.5%, and 26.5%, respectively. IBT significantly increased the HCC-free survival rate (adjusted HR = 0.53, 95% CI = 0.33–0.85, p = 0.008), decreased the risk of hepatic encephalopathy (adjusted HR = 0.40, 95% CI = 0.22–0.73, p = 0.003), ascites (adjusted HR = 0.27, 95% CI = 0.14–0.55, p<0.001), and “any cirrhosis complication” (adjusted HR = 0.33, 95%CI = 0.20–0.54, p<0.001) after adjusting for cirrhosis occurring after the index day. However, the two groups were not significantly different in the survival rate for esophageal varices bleeding. After adjusting for factors that significantly differed between groups, IBT had a lower risk of HCC (adjusted HR, 0.51; 95% CI, 0.32–0.82), esophageal varices bleeding (adjusted HR, 0.43; 95% CI, 0.21–0.88), hepatic encephalopathy (adjusted HR, 0.37; 95% CI, 0.20–0.67), ascites (adjusted HR, 0.27; 95% CI, 0.13–0.55), cirrhosis (adjusted HR, 0.63; 95% CI, 0.43–0.91) and “any cirrhosis complication” (adjusted HR, 0.34; 95% CI, 0.20–0.57) (Adjusted Models 2 in Table 2). The results remained largely unchanged after adjusting all confounders in the multivariable Cox models (Adjusted Models 3 in Table 2). As the prevalence of obesity, HIV, and alcohol intoxication was extremely low (see Table 1), we did not include these variables in the models. No significant interactions were found between IBT and each of the confounders.
For sensitivity analyses, we excluded subjects coinfected with HBV and HIV from the multivariable Cox proportional hazard model testing the effect of IBT on the risk of HCC. The adjusted HR of HCC was 0.50 (95% CI, 0.31–0.81, p = 0.005) for the IBT-treated group as compared with the non-treated group after adjusting for age, sex, diabetes mellitus, ischemic heart diseases, cerebrovascular disease, COPD, chronic renal failure, cirrhosis after the index day, and number of ultrasonography examinations after the index day.
Impact of IBT Duration on the Risk of HCC, Cirrhosis, Hepatic Encephalopathy, Esophageal Varices Bleeding, and Ascites
Compared to those who were not treated, patients who received ≧6 months of IBT had a lower risk of HCC (HR, 0.40; 95% CI, 0.20–0.80), hepatic encephalopathy (HR, 0.24; 95% CI, 0.09–0.64), ascites (HR, 0.27; 95% CI, 0.11–0.66), and “any cirrhosis complication” (HR, 0.32; 95% CI, 0.16–0.61) after adjusting for cirrhosis occurring after the index day. However, a decreased risk was only observed for ascites and “any cirrhosis complication” in patients who received <6 months of IBT compared with those who were not treated (Table 3, Adjusted Model 1). The differences in HCC-free survival, hepatic encephalopathy-free survival, ascites-free survival, cirrhosis-free survival, and any cirrhosis complication-free survival between patients who received ≧6 months of IBT and non-treated ones were statistically significant after further adjustment of factors that differed significantly between two groups (Adjusted Model 2 in Table 3 and Figure 1). After adjusting for all confounders, similar results were found (Adjusted Model 3 in Table 3). No significant interactions were found between IBT and each of the confounders. Of particular note, the prevalence of obesity, HIV, and alcohol intoxication was extremely low; we therefore did not include these variables in the models. In adjusted Model 2 and Model 3, a decreased risk was only observed for ascites and “any cirrhosis complication” in patients who received <6 months of IBT compared with those who were not treated (Table 3).
<6 months IBT vs. no treatment, p = 0.264; ≧6 months IBT vs. no treatment, p = 0.006. IBT = interferon-based treatment. The y-axis is modified, so that it only displays the survival estimates between 0.94 and 1.00.
Discussion
As the progression of chronic HCV infection is slow, the current goal of HCV therapy is defined by a surrogate virological parameter, sustained virologic response (SVR), rather than a clinical endpoint, such as HCC or complications of cirrhosis. SVR is usually considered synonymous with cure and associated with decreasing cirrhosis complications [16], [26], [33], [34], though the data supporting this assumption remain inconclusive. To date, no randomized, controlled trials of IBT have demonstrated a beneficial impact on overall mortality, liver specific mortality or development of HCC, and most of the evidence in favor of IBT is inferred from data of highly selected patients, clinical trials, or cirrhotic patients in tertiary medical centers [7], [9], [11], [12], [14]–[16], [18], [19], [22]–[24], [26], [33], [35]. Therefore, a study based on general population, a large sample size, and long-term observations for complications of cirrhosis is necessary to confirm this assumption. To the best of our knowledge, our study is by far the largest general population-based study that provides evidence to rationalize the use of IBT for patients with HCV infection. Our data clearly demonstrated beneficial effects of IBT on preventing HCC as we found that the HR after adjusting for known prognostic factors in the treated cohort relative to the untreated cohort was 0.5. Similarly, IBT was associated with a 55%, 62%, 72%, 37%, and 65% reduction of risk for esophageal varices bleeding, hepatic encephalopathy, ascites, cirrhosis, and any cirrhosis-associated complication, respectively, after adjustment for prognostic factors.
Our data not only revealed beneficial effects of IBT on preventing HCC, esophageal varices bleeding, hepatic encephalopathy, ascites, cirrhosis, or any cirrhosis-associated complication during an 8-year observation, but also demonstrated that longer treatment duration (at least 6 months) may be required for IBT to exert its protecting effects on HCC, hepatic encephalopathy, and cirrhosis. Moreover, our data provided evidence for the development of clinical practice guidelines as we found that the average number of HCV patients needed to be treated with IBT for 3 months or more for one additional patient to benefit or be harmed. Nonetheless, it must be kept in mind that deteriorations in health-related quality of life and adverse effects of IBT, both are major concerns in current HCV management [36] and important issues in justifying the treatment, were not evaluated in this study. Moreover, whether IBT is cost-effective remains unclear and awaits further studies. Finally, oral antiviral agents for the treatment of HCV have been demonstrated to improve virological responses of patients with chronic HCV infection and are likely to be available in recent years. However, there remains no available study examining the long-term effects of oral antiviral agents on HCV patients, and future studies exploring this important issue are needed.
This study has all the limitations of retrospective cohort studies in attributing causality. First, this study analyzed ex post facto patients groups, and hence certain selection biases may exist in our study sample. For examples, during the period from 2000 to 2008, the Taiwan NHI program only reimbursed IBT for CHC patients who had a histologic confirmation of chronic hepatitis, at least mild fibrosis, and serum alanine aminotransferase (ALT) levels at least twice the upper limit of normal on two occasions within 6 months before the initiation of treatment. Second, pretreatment data on biochemical, virologic response, and histological characteristics were generally lacking in the LHID 2000, and thus were not accounted for when examining the effects of IFN on complications of cirrhosis. Although previous meta-analyses have demonstrated an anti-fibrotic effect of interferon in patients who have not sustained biochemical and virologic responses [37], this conclusion is challenged by recent studies focused on HCV/HIV [38] and advanced hepatitis C nonresponders [10]. Therefore, future studies examining the long-term effects of IBT on patients with different HCV genotypes infection, milder liver fibrosis, non-responders, replapsers, or HIV/HCV infection are needed. Third, although our study demonstrated decreased risks of clinical outcomes in patients receiving ≧3 months of treatments and implied that 6 months of IBT treatment might be required to achieve effects for such clinical outcomes as HCC, encephalopathy, and cirrhosis, the question of whether more than 12 months of IBT would be beneficial for CHC patients remains unclear. Fourth, elderly patients have increasing risks of HCC and advanced fibrosis [39], and several prognostic factors, such sex, diabetes, obesity, and cirrhosis were likely to confound the results of this study. Nevertheless, known prognostic factors were adjusted for in our analyses and IBT was identified as an independent protective factor. Moreover, although Taiwan is endemic in HBV infection and the prevalence of HBV and HIV may impact the outcomes of treatment, excluding subjects co-infected with HBV and HIV did not dramatically change the results. Fifth, because the loss to follow-up rate was significantly higher in the non-IBT treated groups for all endpoints analyzed, the incidence of the endpoints in the non-IBT treated group might have been underestimated due to the fact that death is the major cause of loss to follow-up. However, if this was the case it would work in favor of our hypothesis. Moreover, as the IBT group was indeed under a closer check-up than the non-IBT group, this detection bias might have potentially underestimated the incidence of outcomes in the non-IBT group which in turn potentially underestimated the beneficial effect of IBT; or alternatively, it might have leaded to better health care and behavior in the IBT group and consequently might overestimate the observed beneficial effect of IBT on CHC patients. Therefore, we have examined the number of ultrasonography examinations after the index day, and found patients in the treated cohort received more frequent ultrasonography examinations than those in non-treated cohort (p<0.05). However, adding the number of ultrasonography examinations after the index day into all multivariate models, the conclusions showed that IBT had a lower risk of HCC and cirrhosis-associated complications. Moreover, comparing to non-treated patients, patients receiving IBT ≥6 months have a significantly lower risk of cirrhosis-associated complications and HCC, with the exception of esophageal varices bleeding. Last, the confirmation of HCC and development of liver outcomes were based on claims data, and most patients had a clinical diagnosis based on their image studies or laboratory data, not a histologic diagnosis. Thus the incidence of each outcome might have been underestimated. Moreover, misclassification and measurement errors in drug exposure might have occurred if the patients failed to take the prescribed drugs. Non-compliance is also likely to cause underestimation of the drug effect. Nonetheless, the use of a large nationally representative sample, the dramatically reduced HCC and cirrhosis-associated risk, and the fact that data were collected originally for a different purpose increase the likelihood of the findings being valid, and indicate that these results are likely to be applicable to the whole population and across the different spectrum of CHC patients who meet the criteria for IBT treatment.
In conclusion, our nationwide long-term cohort study demonstrated that IBT was associated with a 50% reduction of risk of HCC and 37% to 72% reductions of risk for complications of cirrhosis in chronic hepatitis C patients, independent of other confounders. Our results may provide evidence to justify the use of IBT in chronic hepatitis C patients and to support the long-term benefits of IBT in reducing the risk of liver cancer and cirrhosis-associated complications.
Supporting Information
Table S1.
International Classification of Diseases, Ninth Revision, Clinical Modification (ICD-9-CM) codes used in the study.
https://doi.org/10.1371/journal.pone.0070458.s001
(DOC)
Table S2.
Interferon-based regimens for treatment of hepatitis C viral infection in Taiwan.
https://doi.org/10.1371/journal.pone.0070458.s002
(DOC)
Table S3.
Distribution of the loss to follow-up rate for each clinical outcome.
https://doi.org/10.1371/journal.pone.0070458.s003
(DOC)
Table S4.
Total person-years of follow-up for each of the clinical outcomes stratified by treatment group.
https://doi.org/10.1371/journal.pone.0070458.s004
(DOC)
Table S5.
Median years of follow-up for each of the clinical outcomes according to treatment group.
https://doi.org/10.1371/journal.pone.0070458.s005
(DOC)
Table S6.
The number of ultrasonography and a-fetoprotein examinations between IBT treated and non-treated cohorts for each clinical outcome.
https://doi.org/10.1371/journal.pone.0070458.s006
(DOC)
Table S7.
Incidence of clinical outcomes according to treatment group.
https://doi.org/10.1371/journal.pone.0070458.s007
(DOC)
Table S8.
The number needed to treat for each clinical outcome.
https://doi.org/10.1371/journal.pone.0070458.s008
(DOC)
Acknowledgments
This study is based in part on data from the National Health Insurance Research Database provided by the Bureau of National Health Insurance, Department of Health, and managed by National Health Research Institutes. The interpretation and conclusions contained herein do not represent those of the Bureau of National Health Insurance, Department of Health, or National Health Research Institutes. Guarantor of the article: PS Tsai had full access to all the data in the study and took responsibility for the integrity of the data and the accuracy of the data analysis.
Author Contributions
Conceived and designed the experiments: CSH CJH PST. Performed the experiments: YCF CJH PST. Analyzed the data: CSH YCF CJH PST. Contributed reagents/materials/analysis tools: YCF CJH PST. Wrote the paper: CSH JHK HHL YCC YCF CJH PST.
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