# Introduction to nph and Usage Instructions

#### Robin Ristl, Nicolas Ballarini

#### 2020-01-08

# Overview

The nph package includes functions to model survival distributions in terms of piecewise constant hazards and to simulate data from the specified distributions.

# Installation

The package is available from CRAN and can be installed directly from R.

    install.packages("nph")

    # For dev version
    # install.packages("devtools")
    devtools::install_github("repo/nph")

# Getting started

Basically, there are three mechanisms for non-proportionality available in this package:

- Disease progression
- Different effect by time intervals
- Subgroups

These scenarios are illustrated in the following figures. Note that the hazard ratio is not constant across time.

# Basics

The functions of the package can be grouped according to their functionality.

Functions for modelling/setting the underlying survival model:

- `hazVFfun`
- `subpop_pchaz`
- `pop_pchaz`

Functions for generating simulated dataset given for a specified survival model:

- `sample_fun`
- `sample_conditional_fun`

Functions for performing statistical tests:

- `logrank.test`
- `logrank.maxtest`

Plotting functions:

- `plot.mixpch`
- `plot_diagram`
- `plot_shhr`

The basic underlying model for the survival mechanism assumes that each patient can be in one of three states: Alive with no progression of disease, Alive with progression of disease, and Dead.

## Creating the population model with pop_pchaz

The first step is to create the population model with the `pop_pchaz` function. As the previous figure shows, there are three hazard rates that need to be defined: the hazard of disease progression \(\lambda_P(t)\), the hazard of death given no progression \(\lambda_P(t)\), and the hazard of death given progression \(\lambda_P(t)\). The arguments `lambdaProgMat`, `lambdaMat1`, and `lambdaMat2` in the `pop_pchaz` function correspond to the three hazard rates, respectively.

The hazard rates are assumed piecewise constant functions across \(k\) time intervals \([t_{j-1}, t_j)\), \(j=1, \ldots,k\) with \(0=t_0<t_1<\ldots<t_k=\infty\). Therefore, the `pop_pchaz` function has also an argument `T` that is a vector to specify \(t_0,t_1,\ldots,t_k\). When `T` is of length 2 (and therefore only one time interval) `lambdaProgMat`, `lambdaMat1`, and `lambdaMat2` are scalars. If `T` is of length > 2, then the `lambdaProgMat`, `lambdaMat1`, and `lambdaMat2` are matrices where the number of columns is equal to the number of time intervals \[\begin{bmatrix}\lambda^{[t_0-t_1)} & \lambda^{[t_1-t_2)} & \ldots &\lambda^{[t_{k-1}-t_k)}\end{bmatrix}.\]

For example, if the patients are followed for two years but the hazards change after the first year, then `T` should be specified as `c(0, 365, 2*365)`. If we assume a hazard rate for death of 0.02 and 0.04 for the first and second year respectively, the we should specify `lambdaMat1 = matrix(c(0.02, 0.04), ncol = 2)`.

Finally, is is also possible to specify different hazard rates for subgroups. The `pop_pchaz` has the argument `p` which is intended to specify the subgroup prevalences. Given \(m\) subgroups with relative sizes \(p_1, p_2, \ldots, p_m\), then the `p` argument should be specified as `c(p_1, p_2, ..., p_m)`. The `lambdaProgMat`, `lambdaMat1`, and `lambdaMat2` then should have the number of row equal to the number of defined subgroups:

\[ \begin{bmatrix} \lambda_1 \\ \lambda_2 \\ \ldots \\ \lambda_m \end{bmatrix}. \]

For example, if patients can be divided into two subgroup with prevalences 0.2 and 0.8 with hazard rates a hazard rate for death of 0.02 and 0.03 thoughout a one year interval, then we define `T = c(0, 365)`, `p = c(0.2, 0.8)` and `lambdaMat1 = matrix(c(0.02, 0.03), nrow = 2)`.

Naturally, it is possible to combine multiple time intervals and subgroups, then the hazard matrices have the form:

Below, we consider an example where there two subgroups and two time intervals. In practice, this situation correspond to the case where there is a delayed effect of the drug. Note that for specifying the hazard matrices, we use the median time to death/progression and use the function `m2r` (also provided in the package) to obtain the hazard rates.

    times <- c(0, 100, 5 * 365)   # Time interval boundaries, in days
    t_resp <- c(0.2, 0.8) #Proportion of subgroups
    B5 <- pop_pchaz(
      T = times,
      lambdaMat1    = m2r(matrix(c(11, 30,
                                   11, 18), byrow = TRUE, nrow = 2)),
      lambdaMat2    = m2r(matrix(c( 9, 20,
                                    9, 11), byrow = TRUE, nrow = 2)),
      lambdaProgMat = m2r(matrix(c( 5, 15,
                                    5,  9), byrow = TRUE, nrow = 2)),
      p = t_resp, discrete_approximation = TRUE
    )

The results object is of class `mixpch`, which has a dedicated plotting function to visualize the survival and hazard functions.

    plot(B5, main = "Survival function")
    plot(B5, fun = "haz", main = "Hazard function")
    plot(B5, fun = "cumhaz", main = "Cumulative Hazard function")

## Creating a simulated dataset with sample_fun

The sample_fun function is designed to generate a simulated dataset that would be obtained from a parallel group randomised clinical trial.

The first step is to create two objects with the (theoretical) survival functions for the treatment and control groups using `pop_pchaz`:

    times <- c(0, 100, 5 * 365)   # Time interval boundaries, in days
    # Treatment group
    B5 <- pop_pchaz(T = times,
                       lambdaMat1    = m2r(matrix(c(11, 30,
                                                    11, 18), byrow = TRUE, nrow = 2)),
                       lambdaMat2    = m2r(matrix(c( 9, 20,
                                                     9, 11), byrow = TRUE, nrow = 2)),
                       lambdaProgMat = m2r(matrix(c( 5, 15,
                                                     5,  9), byrow = TRUE, nrow = 2)),
                       p = c(0.2, 0.8),#Proportion of subgroups
                    discrete_approximation = TRUE
    )
    # Control group
    K5  <- pop_pchaz(T = times,
                        lambdaMat1    = m2r(matrix(c(11, 11), nrow = 1)),
                        lambdaMat2    = m2r(matrix(c( 9,  9), nrow = 1)),
                        lambdaProgMat = m2r(matrix(c( 5,  5), nrow = 1)),
                        p = 1, discrete_approximation = TRUE
    )

Then, using the resulting objects, we use them to generate a dataset with the `sample_fun` function:

    # Study set up and Simulation of a data set until interim analysis at 150 events
    set.seed(15657)
    dat <- sample_fun(K5, B5,
                      r0 = 0.5,                     # Allocation ratio
                      eventEnd = 450,               # maximal number of events
                      lambdaRecr = 300 / 365,       # recruitment rate per day (Poisson assumption)
                      lambdaCens = 0.013 / 365,     # censoring rate per day  (Exponential assumption)
                      maxRecrCalendarTime = 3 * 365,# Maximal duration of recruitment
                      maxCalendar = 4 * 365.25)     # Maximal study duration
    head(dat)
    #>     group inclusion  y yCalendar event adminCens cumEvents
    #> 777     1        26  3        29  TRUE     FALSE         1
    #> 17      1        25 18        43  TRUE     FALSE         2
    #> 367     1         9 40        49  TRUE     FALSE         3
    #> 64      0        42  9        51  TRUE     FALSE         4
    #> 25      0        34 40        74  TRUE     FALSE         5
    #> 708     1       103  7       110  TRUE     FALSE         6
    tail(dat)
    #>     group inclusion   y yCalendar event adminCens cumEvents
    #> 889     1       755 207       962 FALSE      TRUE       450
    #> 893     0       205 757       962 FALSE      TRUE       450
    #> 896     0       814 148       962 FALSE      TRUE       450
    #> 900     1       510 452       962 FALSE      TRUE       450
    #> 907     1       225 737       962 FALSE      TRUE       450
    #> 908     0       717 245       962 FALSE      TRUE       450

## The weighted log-rank test and the max-LRtest

The weighted log-rank test is implemented using the function `logrank.test`, which uses the statistic:

\[ z = \sum_{t\in\mathcal{D}} w(t)(d_{t, ctr} - e_{t,ctr}) / \sqrt{\sum_{t\in\mathcal{D}} w(t)^2 var(d_{t, ctr})}. \]

where \(w(t)\) are the Fleming-Harrington \(\rho-\gamma\) family weights, such that \(w(t)=\widehat{S}(t)^{\rho}(1-\widehat{S}(t))^{\gamma}\). Under the the least favorable configuration in \(H_0\), the test statistic is asymptotically standard normally distributed and large values of \(z\) are in favor of the alternative.

For example, the following code performs the weighted log-rank test using the simulated dataset and \(\rho = 1\) and \(\gamma = 0\).

    logrank.test(time  = dat$y,
                 event = dat$event,
                 group = dat$group,
                 # alternative = "greater",
                 rho   = 1,
                 gamma = 0)
    #> Call:
    #> logrank.test(time = dat$y, event = dat$event, group = dat$group,
    #>     rho = 1, gamma = 0)
    #>
    #>     N Observed Expected (O-E)^2/E (O-E)^2/V
    #> 1 411      267      211      15.2      58.3
    #> 2 385      183      239      13.3      58.3
    #>
    #>  Chisq= 22  on 1 degrees of freedom, p= 3e-06
    #>  rho   =  1 gamma =  0
    # survival::survdiff(formula = survival::Surv(time  = dat$y, event = dat$event) ~ dat$group)

For a set of \(k\) different weight functions \(w_1(t), \ldots, w_k(t)\), the maximum log-rank test statistic is \(z_{max} = \max_{i=1,\ldots,k}z_i\). Under the least favorable configuration in \(H_0\), approximately \((Z_1, \ldots, Z_k) \sim N_k(0, \Sigma)\). The \(p\)-value of the maximum test, \(P_{H_0}(Z_{max} > z_{max})\), is calculated based on this multivariate normal approximation via numeric integration.

The following code performs the maximum log-rank test using four combinations of \(\rho\) and \(\gamma\) for the weights.

    lrmt = logrank.maxtest(
          time  = dat$y,
          event = dat$event,
          group = dat$group,
          rho   = c(0, 0, 1, 1),
          gamma = c(0, 1, 0, 1)
    )
    lrmt
    #> Call:
    #> logrank.maxtest(time = dat$y, event = dat$event, group = dat$group,
    #>     rho = c(0, 0, 1, 1), gamma = c(0, 1, 0, 1))
    #>
    #>  Two sided p-value = 4.91e-08 (Bonferroni corrected: 1.96e-07)
    #>
    #>  Individual weighted log-rank tests:
    #>   Test    z        p
    #> 1    1 5.37 7.99e-08
    #> 2    2 5.24 1.58e-07
    #> 3    3 4.69 2.76e-06
    #> 4    4 5.45 4.91e-08

The individual tests can also be accesed using the `testListe` elements in the resulting object.

    lrmt$logrank.test[[1]]
    #> Call:
    #> logrank.test(time = time, event = event, group = group, alternative = alternative,
    #>     rho = rho[i], gamma = gamma[i])
    #>
    #>     N Observed Expected (O-E)^2/E (O-E)^2/V
    #> 1 411      267      211      15.2      28.8
    #> 2 385      183      239      13.3      28.8
    #>
    #>  Chisq= 28.8  on 1 degrees of freedom, p= 8e-08
    #>  rho   =  0 gamma =  0
    lrmt$logrank.test[[2]]
    #> Call:
    #> logrank.test(time = time, event = event, group = group, alternative = alternative,
    #>     rho = rho[i], gamma = gamma[i])
    #>
    #>     N Observed Expected (O-E)^2/E (O-E)^2/V
    #> 1 411      267      211      15.2       185
    #> 2 385      183      239      13.3       185
    #>
    #>  Chisq= 27.5  on 1 degrees of freedom, p= 2e-07
    #>  rho   =  0 gamma =  1
    lrmt$logrank.test[[3]]
    #> Call:
    #> logrank.test(time = time, event = event, group = group, alternative = alternative,
    #>     rho = rho[i], gamma = gamma[i])
    #>
    #>     N Observed Expected (O-E)^2/E (O-E)^2/V
    #> 1 411      267      211      15.2      58.3
    #> 2 385      183      239      13.3      58.3
    #>
    #>  Chisq= 22  on 1 degrees of freedom, p= 3e-06
    #>  rho   =  1 gamma =  0
    lrmt$logrank.test[[4]]
    #> Call:
    #> logrank.test(time = time, event = event, group = group, alternative = alternative,
    #>     rho = rho[i], gamma = gamma[i])
    #>
    #>     N Observed Expected (O-E)^2/E (O-E)^2/V
    #> 1 411      267      211      15.2       806
    #> 2 385      183      239      13.3       806
    #>
    #>  Chisq= 29.8  on 1 degrees of freedom, p= 5e-08
    #>  rho   =  1 gamma =  1