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Clinical trial simulation to evaluate power to compare the antiviral effectiveness of two hepatitis C protease inhibitors using nonlinear mixed effect models: a viral kinetic approach
 Cédric Laouénan^{1, 2}Email author,
 Jeremie Guedj^{1} and
 France Mentré^{1, 2}
https://doi.org/10.1186/147122881360
© Laouénan et al.; licensee BioMed Central Ltd. 2013
Received: 26 December 2012
Accepted: 12 April 2013
Published: 25 April 2013
Abstract
Background
Models of hepatitis C virus (HCV) kinetics are increasingly used to estimate and to compare in vivo drug’s antiviral effectiveness of new potent antiHCV agents. Viral kinetic parameters can be estimated using nonlinear mixed effect models (NLMEM). Here we aimed to evaluate the performance of this approach to precisely estimate the parameters and to evaluate the type I errors and the power of the Wald test to compare the antiviral effectiveness between two treatment groups when data are sparse and/or a large proportion of viral load (VL) are below the limit of detection (BLD).
Methods
We performed a clinical trial simulation assuming two treatment groups with different levels of antiviral effectiveness. We evaluated the precision and the accuracy of parameter estimates obtained on 500 replication of this trial using the stochastic approximation expectationapproximation algorithm which appropriately handles BLD data. Next we evaluated the type I error and the power of the Wald test to assess a difference of antiviral effectiveness between the two groups. Standard error of the parameters and Wald test property were evaluated according to the number of patients, the number of samples per patient and the expected difference in antiviral effectiveness.
Results
NLMEM provided precise and accurate estimates for both the fixed effects and the interindividual variance parameters even with sparse data and large proportion of BLD data. However Wald test with small number of patients and lack of information due to BLD resulted in an inflation of the type I error as compared to the results obtained when no limit of detection of VL was considered. The corrected power of the test was very high and largely outperformed what can be obtained with empirical comparison of the mean VL decline using Wilcoxon test.
Conclusion
This simulation study shows the benefit of viral kinetic models analyzed with NLMEM over empirical approaches used in most clinical studies. When designing a viral kinetic study, our results indicate that the enrollment of a large number of patients is to be preferred to small population sample with frequent assessments of VL.
Keywords
Background
Chronic infection with Hepatitis C Virus (HCV) affects 130–200 million people worldwide [1]. It is the leading cause of cirrhosis, liver cancer and liver transplants which result in 350,000 deaths worldwide [2]. HCV is divided into 6 genotypes, with genotype 1 being the hardest to treat and the most prevalent in Western countries. The goal of treatment is to achieve a sustained virologic response (SVR), marker of viral eradication, assessed by a viral load HCV RNA (VL) below the limit of detection (LOD) six months after cessation of therapy. Until 2011, the only available treatment was based on weekly injections of pegylated interferon (pegIFN) and daily oral ribavirin (RBV) during 48 weeks, with SVR rate lower than 50% in treatmentnaïve HCV genotype 1 patients [3].
In 2011, the approval of two protease inhibitors (PI), telaprevir and boceprevir, in combination with pegIFN/RBV (triple therapy), marked a milestone for antiHCV therapy with SVR rates larger than 70% in treatmentnaïve HCV genotype 1 patients [4, 5]. Dozens of compounds targeting different viral proteins are currently in different stages of clinical trials, raising the expectation that several IFNfree regimens might be available in the coming years.
Viral kinetic modeling aims at characterizing the main mechanisms that govern the virologic response to treatment using mathematical models. Following the recommendations of the Food and Drug Administration [6], this approach has been increasingly used in phase 1/2 of clinical development to estimate viral kinetic parameters and to evaluate drug antiviral effectiveness in vivo[7, 8]. Parameter estimation is often achieved using nonlinear mixed effect models (NLMEM) [9]. The popularity of this approach is due to the fact that it optimizes the information available by borrowing strength from the whole sample to provide precise estimation of the parameters, including covariate effects [10–12]. Moreover it naturally accounts for the information brought by VL data below the limit of detection (BLD) and reduces the bias in parameter estimation as compared to empirical approaches where BLD data are ignored or assigned to half the LOD [10, 13, 14].
So far, viral kinetic models and NLMEM have mostly been used in phase 1/2 clinical trials with large number of patients and/or frequent assessment of VL data within each patient. However in most clinical trials, in particular when they are not sponsored by the industry, it is not possible to hospitalize patients and to get frequent viral load samples. In this challenging context, the capacity of NLMEM to precisely estimate viral kinetic parameters is not known. In particular the performance of tests used to assess the effect of a covariate which have good asymptotic properties (Wald test, likelihood ratio test or score test) is not warranted when one is far from the asymptotic conditions. For instance an inflation of the type I error has been reported in another clinical context where data were sparse [15]. With the new potent triple therapies against HCV the amount of information available may also be limited by the fact that a large proportion of VL data are below LOD.
Here our goal was to evaluate the capacity of NLMEM to precisely estimate the parameters of viral kinetic models when there is a large proportion of BLD data and a limited number of data per patient. In particular we aimed to evaluate by simulation the type I errors and the power of the Wald test to compare the antiviral effectiveness of two groups receiving different triple therapies (noted PIA and PIB in the following). Parameter estimation and Wald test property were evaluated according to the number of patients, the number of samples per patient and the expected difference in antiviral effectiveness between the two treatment groups.
Methods
Viral kinetic model
where T represents the density of target cells that can be infected by virus measured as HCV RNA (V), with rate constant b. In the model, infected cells (I) die or lose their infected state with rate constant δ and produce virions at constant rate p per cell. Virions are assumed to be cleared with rate constant c. As it is done usually when considering short term VL data we assumed that the target cell level is constant throughout the study period and remains at its pretreatment steady state value T _{ 0 } = cδ/pb[17, 18].
Treatment is assumed to reduce the average rate of viral production per cell from p to p(1–ϵ), where ϵ represents the constant drug effectiveness, i.e., ϵ = 0.990 implying the drug is 99% effective in blocking viral production. If all parameters including treatment effectiveness are constant over time this model predicts that VL will fall in a biphasic manner [16], with a rapid first phase of viral decline with rate approximately equal to c lasting for a couple of days and with the magnitude viral decline depending on ϵ, and a second slower but persistent second phase of viral decline with rate ϵδ. Hence, for potent therapies for which ϵ is close to 1, the secondphase slope will be approximately δ.
Lastly mathematical analysis shows that if ϵ is constant, p and b do not intervene in the VL equation and thus where ignored in the following without loss of generality [19].
Statistical model

f is the nonlinear model,

Φ _{ i } is the vector of individual parameters of length p where p is the number of parameters,

e _{ ij } is the residual error assumed to follow a normal distribution with mean 0 and variance σ ^{2},

h is the transformation of the vector of parameters that make them normally distributed,

μ is the vector of fixed effects,

β is the vector of coefficient of the only covariate studied i.e. the difference of effectiveness between PIA and PIB (with T _{ i } = 0 if treatment is PIA and T _{ i } = 1 if treatment is PIB),

η _{ i } is the vector of random effects independent of e _{ i }, and are supposed to be independent, with diagonal variancecovariance matrix $\mathrm{\Omega}=\mathit{diag}\phantom{\rule{0.5em}{0ex}}\left({\omega}_{1}^{2},\dots ,{\omega}_{p}^{2}\right)$.
It is assumed that h is the logarithm transformation for V _{ 0 }, δ and c and the logit transformation for ϵ.
Parameter values
Value, distribution and interindividual standard deviation of population parameters from data with patients treated by monotherapy of PIA [7]
V _{ 0 }(IU/mL)  c(day^{1})  δ(day^{1})  ϵ  σ (log_{10}IU/mL)  

Fixed effect  2.68 10^{6}  13.4  0.58  0.999  0.19 
Transformation  lognormal  lognormal  lognormal  logisticnormal   
Interindividual standard deviation (ω)  1.09  0.25  0.25  0.61   
Clinical trial simulation
Parameter estimation
Data of each simulated trial were analyzed using MONOLIX version 4.2 (http://www.lixoft.eu/monolix/productmonolixoverview/) [21], a software devoted to maximum likelihood estimation of parameters in NLMEM using an extension of the stochastic approximation expectationapproximation (SAEM) algorithm [22, 23]. Of note one advantage of maximum likelihood estimation (noted “ML” in the following) is that it takes into account the information brought by BLD data [10]. We compared accuracy and precision of parameter estimations obtained with those that would be obtained if all data were observed with no BLD data at all (referred as “all data”).
The accuracy and the precision of parameter estimates were evaluated using RB and RRMSE, respectively.
Detection of a difference in antiviral effectiveness
We analyzed for each scenario the ability to detect a difference of antiviral effectiveness between the two PIs. Given that treatment antiviral effectiveness was estimated on a logistic scale we defined accordingly the difference of effectiveness between the two PIs, β, as β = logit(ϵ ^{ A }) − logit(ϵ ^{ B }). For each simulated dataset, the estimated value of $\beta ,\widehat{\beta}$, was obtained along with its (estimated) standard error, $S{E}_{\widehat{\beta}}$. Then the Wald test statistics given by $\frac{\widehat{\beta}}{S{E}_{\widehat{\beta}}}$ was calculated and the null hypothesis “H_{0}: β = 0” was rejected at the level of 5% if $\left\frac{\widehat{\beta}}{S{E}_{\widehat{\beta}}}\right>1.96$. Thus in scenarios where ϵ ^{A} = ϵ ^{B} = 0.999 and therefore β = 0, the type I error was given by the proportion of dataset among the 500 simulated that led to reject H_{0}. Similarly the power to detect a difference in treatment antiviral effectiveness was calculated in scenarios where β ≠ 0 and was given by the proportion of datasets among the 500 simulated that led to reject H_{0.} With ϵ ^{A} = 0.999 and with values of ϵ ^{B} equal to 0.998, 0.995 and 0.990, β were equal to 0.7, 1.6 and 2.3, respectively. Type I error and power were evaluated with all designs describe above and consistent with previous analysis [15, 24], we expect an inflation of the type I error with the Wald test. To ensure a type I error of 5%, we define for each design a correction threshold as the 5^{th} percentile of the distribution of the pvalues of the test under H_{0} for the 500 simulated dataset. Then we used that corrected threshold as a limit of significance in the evaluation of the tests under H_{1} to compute the corrected power [15, 25]. Furthermore we evaluated type I error with 2 larger sample size to approach asymptotic conditions with: n_{tot} = 350 (N = 50 and n = 7) and n_{tot} = 700 (N = 100 and n = 7). Lastly, the power to detect a difference in treatment effectiveness between the two PIs was compared with the one obtained by standard empirical approaches where the difference in viral decline at day 14 between two treatments is tested by a non parametric twosided Wilcoxon test.
Results
Parameter estimation
First we evaluated the impact of having a large proportion of BLD data on the precision of parameter estimates. Proportions of BLD data were equal to 19.3% and 88.3% at days 7 and 14 with ϵ = 0.999, 10.2% and 80.7% with ϵ = 0.998, 3.9% and 66.7% with ϵ = 0.995, 1.5% and 54.3% with ϵ = 0.990, respectively (Figure 1). For that purpose we compared the parameters estimation with all data or ML with the design N = 30 and n = 7 and assuming a lower effectiveness for PIB than PIA (ϵ ^{A} = 0.999 vs ϵ ^{B} = 0.990).
Relative bias (RB) (%) and relative root mean square error (RRMSE) (%) of the estimated parameters evaluated from 500 simulated datasets
All data (n = 7 VL)  ML (n = 7 VL)  ML (n = 5 VL)  

RB (%)  RRMSE (%)  RB (%)  RRMSE (%)  RB (%)  RRMSE (%)  
log_{10}(V _{ 0 }) (IU/mL)  0.1  1.0  0.2  1.0  0.1  1.0 
c (day^{1})  1.0  4.3  0.6  4.1  34.1  78.8 
δ (day^{1})  0.2  3.2  0.8  3.7  0.6  3.7 
log_{10}(1ϵ)  0.1  3.2  0.4  3.1  0.3  3.6 
β  0.4  8.5  −0.5  8.5  0.4  9.9 
_{ω} ^{2} _{vo}  −0.4  18.9  −1.0  19.0  −0.5  19.3 
_{ω} ^{2} _{c}  −4.6  31.5  −10.9  32.9  236.6  358.3 
_{ω} ^{2} _{δ}  −3.0  19.8  −2.3  24.5  −2.4  24.9 
_{ω} ^{2} _{ϵ}  −2.6  32.2  −4.5  32.0  −9.9  36.3 
σ  −0.03  5.3  −0.7  6.2  −1.3  8.0 
Type I error of the Wald test
Power to detect a difference in antiviral effectiveness
Power (%) to detect a difference of effectiveness between PIA and PIB according to the study design and the effectiveness of PIB ( ϵ ^{ B } ), assuming ϵ ^{ A } = 0.999 and a limit of detection (“ML data”)
ϵ ^{B}  0.998  0.995  0.990  0.998  0.995  0.990  0.998  0.995  0.990  

Small sample size  Design*  N = 10 and n = 7  N = 14 and n = 5  N = 10 and n = 5  
n_{tot} = 70  n_{tot} = 70  n_{tot} =50  
Wald test (uncorrected)  62.2  99.8  100  61.8  100  100  55.2  98.8  100  
Wald test (corrected)  44.2  98.4  100  50.4  100  100  35.8  95.8  100  
Wilcoxon test  6.6  11.2  26.8  4.4  15.6  39.0  6.6  11.2  26.8  
Design*  N = 20 and n = 7  N = 28 and n = 5  N = 20 and n = 5  
n_{tot} = 140  n_{tot} = 140  n_{tot} = 100  
Middle sample size  Wald test (uncorrected)  83.4  100  100  86.8  100  100  77.8  100  100 
Wald test (corrected)  69.0  100  100  78.0  100  100  58.8  100  100  
Wilcoxon test  7.0  23.0  50.4  6.8  30.4  64.6  7.0  23.0  50.4  
Large sample size  Design*  N = 30 and n = 7  N = 42 and n = 5  N = 30 and n = 5  
n_{tot} = 210  n_{tot} = 210  n_{tot} = 150  
Wald test (uncorrected)  94.0  100  100  86.8  100  100  89.4  100  100  
Wald test (corrected)  89.2  100  100  82.6  100  100  82.6  100  100  
Wilcoxon test  7.4  31.0  67.0  9.2  43.8  85.0  7.4  31.0  67.0 
Lastly, we compared these results with the power achieved by comparing the mean viral decline at day 14 between both groups using a Wilcoxon test. The power of Wilcoxon test was on average lower of 44% as compared to the one achieved with viral kinetic model and NLMEM with ϵ ^{B} = 0.995 or 0.998 (Table 3). Even when PIB’s and PIA’s antiviral effectivenesses were assumed to be 0.990 and 0.999, respectively, corresponding to a 10fold difference in the viral production under treatment, the power of the Wilcoxon test was only equal to 67% with N = 30, compare to 100% with the Wald test (Table 3). It should be noted that the type I error of the Wilcoxon test, which is a non parametric test, was not inflated (5.2% with the design N = 10 for example).
Discussion
The goal of this study was to evaluate the capacity of NLMEM to provide precise and accurate estimates of viral kinetic parameters when only sparse data with a large proportion of BLD data are available. In particular we aimed to evaluate the ability of this approach to correctly reject or not the null hypothesis of equal treatment effectiveness when two groups with different antiviral strategies are compared.
Our results showed that NLMEM provide very precise and accurate estimates for both the fixed effects and the interindividual variance parameters, even when only 5 data points (at days 0, 2, 3, 7 and 14) were available within each patient. This allowed circumventing the need for intensive VL sampling measurements at treatment initiation, which are difficult to obtain in current clinical practice. Of note the viral clearance rate, c and its associated variability ω_{c}, were poorly estimated in this sparse initial sampling. However this parameter is mostly involved in the initial rate of viral decline and thus a poor estimation of c did not substantially deteriorate the estimation of the other parameters (Table 2).
By comparing the results obtained with and without a LOD for VL, we demonstrated that maximum likelihood appropriately handle BLD, consistent with results found previously [10]. The conclusion was somewhat different when considering the outcome of Wald test for comparing antiviral effectiveness. In this case the lack of information due to BLD contributed to an inflation of the type I error as compared to the results obtained with no LOD of VL, suggesting that the development of realtime PCR assays with lower LOD may improve the estimation of viral kinetic parameters. Interestingly, even when there was no LOD of VL, we still found that the type I error was inflated when the number of observations n_{tot} was lower than 140. This suggests that the outcome of Wald test should be taken with caution when the number of patients is low and in that case we suggested to use a threshold correction for the Wald test to limit the impact of this inflation. Here we used an empirical threshold correction but other corrections exist such as the Galland correction or the permutation test [15]. On the other hand the power of the Wald test (corrected or not) was found to be very high, especially when compared with that obtained using a Wilcoxon test on the mean viral decline at day 14. This result clearly shows the benefit of viral kinetic analyzed with NLMEM over empirical approaches done in most clinical studies. Although better results may be obtained by comparing the viral decline at earlier time points (such as day 2 or 7) the power of the Wilcoxon test remained lower than those achieved by modeling approach (not shown). Consistent with results found elsewhere, the power increases when the number of observations per patient increases and was much less sensitive to the number of measurements within each patient [26]. From a clinical standpoint this finding indicates that the enrollment of a large population of study is to be preferred to small population sample with frequent assessments of VL.
We focused here on the properties of the Wald test and further studies would be needed to study how these results apply to other tests that require more computation time, such as likelihood ratio tests (LRT) or score test. Interestingly previous simulation studies using the SAEM algorithm in MONOLIX showed that the outcomes of these tests were largely comparable [15]. Of note this result may not hold when other estimation methods are used and for instance the outcomes of Wald test and LRT were found to be different when using the FOCEI algorithm in NONMEM version 7 [15]. Indeed the Wald test had a lower power than LRT with FOCEI, which was probably due to the poor estimation of the standard error of the covariate effect [25]. The advantage of the Wald test is that results are immediately obtained and do not require to compute the likelihood or its derivatives, as done for the LRT and the score test. Computation time needed by simulations could be largely reduced by using information theory and approximations to derive Fisher information matrix. For instance the software PFIM uses a first order approximation of the likelihood and, under this approximation, an analytical form of the Fisher matrix can be obtained [27]. Thus the expected variance of viral kinetic parameters could be obtained without the intensive simulations done here. Although such approximations worked well even with limited number of patients [11], it does not take into account BLD data and hence could underestimate the standard error when a large proportion of data are BLD. It should be noted that optimal design theory predicts that an increase of variances in random effect may deteriorate the precision of parameter estimates and the power of the Wald test. However this possibility was not investigated in this study where the interindividual variance parameters were fixed.
Here we focused on the comparison of treatment antiviral effectiveness in the first two weeks of treatment. On this short time scale the standard biphasic model of viral kinetics has been shown to provide a good fit to the data [7, 16]. However more complex models may be needed to fit longterm VL data, such as models that relax the assumption of constant target cells and/or account for the emergence of treatment resistant viruses [28, 29]. Moreover viral decline during PI therapy is faster than what is observed with IFNbased therapy [30]. This feature is captured in the standard biphasic model by assuming that PIs lead to an enhancement of the treatment effectiveness, ϵ, and of the clearance rate of infected cells, δ[7, 29, 31]. Consistent with this observation we set here large mean values for both ϵ and δ, equal to 0.999 and 0.58 day^{1} as compared to 0.92 and 0.14 day^{1} with IFNbased therapy, respectively [30]. However this dual mode of action of PIs may be integrated in a more physiological way by using new multiscale viral kinetic models that explicitly integrate the effect of PIs on the intracellular viral dynamics [9].
Although the use of NLMEM has been shown to provide very precise and accurate estimates of the parameters even in presence of sparse designs, it should be acknowledged that these estimates are done on the population parameters, i.e., the mean and the variance of parameters in the population. How NLMEM also allow precise and accurate estimation of the individual parameters for individualized treatment duration remains to be evaluated.
Conclusion
Compared with standard approach (with Wilcoxon test), modeling approach (with Wald test) provides very precise and accurate estimates of viral kinetic parameters and a more powerful tool to detect a difference in early viral kinetic profile of two PIs with different antiviral efficacy, even with sparse initial sampling or small number of patients. When designing a viral kinetic study, our results indicate that the enrollment of a larger number of patients is to be preferred to smaller sample size with more frequent assessments of viral load. We showed that a threshold correction is needed for the Wald test with small samples especially if there are many BLD data.
Declarations
Acknowledgements
The authors thank IFR02 and Hervé Le Nagard for the use of the Centre de Biomodélisation.
Authors’ Affiliations
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