An R package to fit excess hazard models, with or without proportional population hazards assumption. The baseline excess hazard could be a piecewise constant function or a B-splines. When B-splines is choosen for the baseline excess hazard, the user can specify some covariates which have a time-dependent effect (using “bsplines”) on the baseline excess hazard. The user can also specify if the framework corresponds to the classical excess hazard modeling, i.e. assuming that the expected mortality of studied individuals is appropriate. He can also consider two other framework: first, the expected mortality available in the life table is not accurate and requires taking into account an additional variable in the life table with a proportional Touraine et al. (2020) or non-proportional (Mba et al. (2020) effect; second, there is a non-comparability source of bias in terms of expected mortality of selected individuals in a clinical trials Goungounga et al. (2019).
(Here’s the abstract from Touraine et al. paper: Relative survival methods used to estimate the excess mortality of cancer patients rely on the background (or expected) mortality derived from general population life tables. These methods are based on splitting the observed mortality into the excess mortality and the background mortality. By assuming a regression model for the excess mortality, usually a Cox-type model, one may investigate the effects of certain covariates on the excess mortality. Some covariates are cancer-specific whereas others are variables that may influence the background mortality as well. The latter should be taken into account in the background mortality to avoid biases in estimating their effects on the excess mortality. Unfortunately, the available life table might not include such variables and, consequently, might provide inaccurate values of the background mortality. We propose a model that uses multiplicative parameters to correct potentially inaccurate background mortality. The model can be seen as an extension of the frequently used Estève model because we assume a Cox-type model for the excess mortality with a piecewise constant baseline function and introduce additional parameters that multiply the background mortality. The original and the extended model are compared, first in a simulation study, then in an application to colon cancer registry data.
A related software package can be found at a gitlab webpage or at https://CRAN.R-project.org/package=xhaz.
The most recent version of xhaz can be installed
directly from the repository using the devtools package
devtools::install_gitlab("/biostat_sesstim/xhaz")xhaz depends on the stats,
survival, optimParallel, optimx,
numDeriv, statmod, gtools and
splines packages which can be installed directly from
CRAN.
It also utilizes survexp.fr, the R package containing
the french life table. For example, to install survexp.fr
follow the instructions available at the RStudio page on R
and survexp.fr.
First, install the R package via github
devtools::install_github("rstudio/survexp.fr")Then, when these other packages are installed, please load the
xhaz R package.
library(xhaz)## Le chargement a nécessité le package : statmod
## Le chargement a nécessité le package : survivalWe illustrate the Esteve model using a simulated dataset from the original Touraine et al. (2020) paper. This dataset is comprised of 2,000 patients with an information regarding their race as this information can impact the patient background mortality. The US life table can be used for the estimation of the model parameters.
data("simuData", package = "xhaz")
head(simuData)## age agec sex race date time status time_year
## 1 50.52825 -1.3186092 male black 1990-10-21 72.00000 0 6.000000
## 2 62.50834 -0.4380647 male black 1990-07-17 72.00000 0 6.000000
## 3 64.49190 -0.2922719 male black 1990-10-18 20.15947 1 1.679956
## 4 48.23570 -1.4871131 male white 1990-12-06 13.78553 1 1.148794
## 5 31.71262 -2.7015697 male black 1990-01-20 72.00000 0 6.000000
## 6 31.11493 -2.7455005 male black 1990-01-17 18.73011 1 1.560842dim(simuData)## [1] 2000 8levels(simuData$sex) <- c("male", "female")
interval <- c(0, 0.718, 1.351, 2.143, 3.601, 6)
fit.estv1 <- xhaz(formula = Surv(time_year, status) ~ agec + race,
data = simuData,
ratetable = survexp.us,
interval = interval,
rmap = list(age = 'age', sex = 'sex', year = 'date'),
baseline = c("constant"),
pophaz = "classic")
fit.estv1## Call:
## xhaz(formula = Surv(time_year, status) ~ agec + race, data = simuData,
## ratetable = survexp.us, rmap = list(age = "age", sex = "sex",
## year = "date"), baseline = c("constant"), pophaz = "classic",
## interval = interval)
##
##
## coef se(coef) lower 0.95 upper 0.95 z Pr(>|z|)
## agec 0.3340 0.0384 0.2588 0.4092 8.70 < 2e-16 ***
## racewhite -0.5737 0.1422 -0.8524 -0.2949 -4.03 5.5e-05 ***
## [0-0.72[ 0.1577 0.0124 0.1335 0.1820 12.74 < 2e-16 ***
## [0.72-1.35[ 0.2317 0.0171 0.1981 0.2652 13.52 < 2e-16 ***
## [1.35-2.14[ 0.2226 0.0168 0.1897 0.2556 13.24 < 2e-16 ***
## [2.14-3.6[ 0.1489 0.0122 0.1250 0.1728 12.21 < 2e-16 ***
## [3.6-6[ 0.1216 0.0107 0.1007 0.1426 11.37 < 2e-16 ***
## ---
## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
##
##
## Excess hazard hazard ratio(s)
## (proportional effect variable(s) for exess hazard ratio(s))
## exp(coef) lower 0.95 upper 0.95
## agec 1.3965 1.2953 1.5056
## racewhite 0.5635 0.4264 0.7446
##
## number of observations: 2000; number of events: 1375
## Likelihood ratio test: 103 on 7 degree(s) of freedom, p=0The new parameter to be added to xhaz() function is
add.rmap: it allows to specify the additional variable for
the life table needed for the estimation of the excess hazard
parameters. This model concerns that proposed by Touraine et al
(2020).
fit.corrected1 <- xhaz(formula = Surv(time_year, status) ~ agec + race,
data = simuData,
ratetable = survexp.us,
interval = interval,
rmap = list(age = 'age', sex = 'sex', year = 'date'),
baseline = "constant", pophaz = "corrected",
add.rmap = "race")
fit.corrected1## Call:
## xhaz(formula = Surv(time_year, status) ~ agec + race, data = simuData,
## ratetable = survexp.us, rmap = list(age = "age", sex = "sex",
## year = "date"), baseline = "constant", pophaz = "corrected",
## add.rmap = "race", interval = interval)
##
##
## coef se(coef) lower 0.95 upper 0.95 z Pr(>|z|)
## agec 0.2942 0.0798 0.1379 0.4506 3.69 0.00023 ***
## racewhite -0.2082 0.1941 -0.5887 0.1723 -1.07 0.28000
## [0-0.72[ 0.1428 0.0205 0.1026 0.1829 6.97 3.2e-12 ***
## [0.72-1.35[ 0.2143 0.0248 0.1657 0.2629 8.65 < 2e-16 ***
## [1.35-2.14[ 0.2067 0.0264 0.1549 0.2585 7.83 5.0e-15 ***
## [2.14-3.6[ 0.1324 0.0240 0.0853 0.1796 5.51 3.6e-08 ***
## [3.6-6[ 0.1087 0.0238 0.0620 0.1554 4.56 5.1e-06 ***
## log(alpha.black) 0.3132 0.3068 -0.2880 0.9145 1.02 0.31000
## log(alpha.white) -0.9172 1.0303 -2.9365 1.1021 -0.89 0.37000
## ---
## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
##
##
## Excess hazard hazard ratio(s)
## (proportional effect variable(s) for exess hazard ratio(s))
## exp(coef) lower 0.95 upper 0.95
## agec 1.3421 1.1478 1.569
## racewhite 0.8121 0.5551 1.188
##
## and corrected scale parameters on population hazard
## exp(coef) lower 0.95 upper 0.95
## alpha.black 1.3679 0.74973 2.496
## alpha.white 0.3996 0.05305 3.010
##
## number of observations: 2000; number of events: 1375
## Likelihood ratio test: 14 on 9 degree(s) of freedom, p=0.124The new parameter to be added to xhaz function is
add.rmap.cut: it furthermore allows to specify that the
additional variable have a non proportional effect on the background
mortality. This excess hazard model concerns that proposed by Mba et al
(2020).
# An additionnal cavariate (here race) missing in the life table is
# considered by the model with a breakpoint at 75 years
fit.corrected2 <- xhaz(formula = Surv(time_year, status) ~ agec + race,
data = simuData,
ratetable = survexp.us,
interval = interval,
rmap = list(age = 'age', sex = 'sex', year = 'date'),
baseline = "constant", pophaz = "corrected",
add.rmap = "race",
add.rmap.cut = list(breakpoint = TRUE, cut = 75))
fit.corrected2## Call:
## xhaz(formula = Surv(time_year, status) ~ agec + race, data = simuData,
## ratetable = survexp.us, rmap = list(age = "age", sex = "sex",
## year = "date"), baseline = "constant", pophaz = "corrected",
## add.rmap = "race", add.rmap.cut = list(breakpoint = TRUE,
## cut = 75), interval = interval)
##
##
## coef se(coef) lower 0.95 upper 0.95 z
## agec 0.2699 0.1020 0.0701 0.4697 2.65
## racewhite -0.3291 0.2983 -0.9138 0.2557 -1.10
## [0-0.72[ 0.1248 0.0249 0.0760 0.1735 5.02
## [0.72-1.35[ 0.1771 0.0286 0.1211 0.2331 6.20
## [1.35-2.14[ 0.1705 0.0302 0.1114 0.2297 5.65
## [2.14-3.6[ 0.1034 0.0293 0.0460 0.1607 3.53
## [3.6-6[ 0.0709 0.0267 0.0185 0.1233 2.65
## log(alpha.black_(30.9,75]) 1.2886 0.1955 0.9054 1.6719 6.59
## log(alpha.black_(75,90.9]) 0.6061 0.2359 0.1437 1.0685 2.57
## log(alpha.white_(30.9,75]) 1.0259 0.4242 0.1945 1.8573 2.42
## log(alpha.white_(75,90.9]) -0.2266 0.4818 -1.1708 0.7176 -0.47
## Pr(>|z|)
## agec 0.00810 **
## racewhite 0.27000
## [0-0.72[ 5.3e-07 ***
## [0.72-1.35[ 5.7e-10 ***
## [1.35-2.14[ 1.6e-08 ***
## [2.14-3.6[ 0.00041 ***
## [3.6-6[ 0.00800 **
## log(alpha.black_(30.9,75]) 4.4e-11 ***
## log(alpha.black_(75,90.9]) 0.01000 **
## log(alpha.white_(30.9,75]) 0.01600 *
## log(alpha.white_(75,90.9]) 0.64000
## ---
## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
##
##
## Excess hazard hazard ratio(s)
## (proportional effect variable(s) for exess hazard ratio(s))
## exp(coef) lower 0.95 upper 0.95
## agec 1.3098 1.073 1.600
## racewhite 0.7196 0.401 1.291
##
## and corrected scale parameters on population hazard
## (non proportional correction using breakpoint approach)
##
## exp(coef) lower 0.95 upper 0.95
## alpha.black_(30.9,75] 3.6278 2.4729 5.322
## alpha.black_(75,90.9] 1.8333 1.1546 2.911
## alpha.white_(30.9,75] 2.7896 1.2147 6.406
## alpha.white_(75,90.9] 0.7972 0.3101 2.049
##
##
## number of observations: 2239; number of events: 1491
## Likelihood ratio test: 7.24 on 11 degree(s) of freedom, p=0.779We can compare the output of these two models using AIC or BIC criteria.
AIC(fit.estv1)## [1] 6767.122AIC(fit.corrected1)## [1] 6766.209BIC(fit.estv1)## [1] 6753.122BIC(fit.corrected1)## [1] 6748.209A statistical comparison between two nested models can be performed
with a likelihood ratio test calculated by function anova
method implemented in xhaz.
As an example, say that we want to test whether we can drop all the complex terms in the Mba model compared to the Touraine model.
As in survival package, We compare the two models using
anova(), i.e.,
anova(fit.corrected1, fit.corrected2)## Assumption: Model 1 nested within Model 2
##
## Likelihood ratio test
## Model 1:
## Surv(time_year, status) ~ agec + race
## Model 2:
## Surv(time_year, status) ~ agec + race
## Model.df loglik df Chisq Pr(>Chisq)
## [1,] 9.0 -3374.1 NA NA NA
## [2,] 11.0 -3528.7 2.0 154.56 < 2.2e-16 ***
## ---
## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1Note that the user is responsible to supply appropriately nested
excess hazard models such that the LRT to be valid. The result suggests
that we could use the Mba model with non-proportional population
hazards, correcting for the life table with additional stratification on
the variable race.
One could be interested to the prediction of net survival and excess
hazard of the individual with the same characteristics as individual 1
on the the simuData (age 50.5, race black)
#only add Surv variables (time_year and status) to have them in the new.data.
#They are not used for the prediction
simuData[1,]## age agec sex race date time status time_year
## 1 50.52825 -1.318609 male black 1990-10-21 72 0 6newdata1 <-
expand.grid(
race = factor("black",
levels = levels(simuData$race)),
agec = simuData[1, "agec"], #i.e age 50.5 years
time_year = 0,
status = 0
)
predict_mod1 <- predict(object = fit.estv1,
new.data = newdata1,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
predict_mod2 <- predict(object = fit.corrected1,
new.data = newdata1,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
predict_mod3 <- predict(object = fit.corrected2,
new.data = newdata1,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
old.par <- par(no.readonly = TRUE)
par(mfrow = c(2, 1))
plot(
predict_mod1,
what = "survival",
xlab = "time since diagnosis (year)",
ylab = "net survival",
ylim = c(0, 1),
main = "Estève Model"
)
par(new = TRUE)
plot(
predict_mod2,
what = "survival",
xlab = "",
ylab = "",
ylim = c(0, 1),
lty = 2,
lwd = 2# main = "Touraine Model"
)
par(new = TRUE)
plot(
predict_mod3,
what = "survival",
xlab = "",
ylab = "",
ylim = c(0, 1),
lty = 3,
lwd = 3#main = "Mba Model"
)
legend(
"bottomleft",
legend = c("Esteve Model",
"Touraine Model",
"Mba Model"),
lty = c(1, 2 , 3),
lwd = c(1, 2 , 3)
)
plot(
predict_mod1,
what = "hazard",
xlab = "time since diagnosis (year)",
ylab = "excess hazard",
ylim = c(0, 0.30),
lty = 1
)
par(new = TRUE)
plot(
predict_mod2,
what = "hazard",
xlab = "",
ylab = "",
ylim = c(0, 0.30),
lty = 2,
lwd = 2
)
par(new = TRUE)
plot(
predict_mod3,
what = "hazard",
xlab = "",
ylab = "",
ylim = c(0, 0.30),
lty = 3,
lwd = 3
)
legend(
"topright",
legend = c("Esteve Model",
"Touraine Model",
"Mba Model"),
lty = c(1, 2 , 3),
lwd = c(1, 2 , 3)
)
par(old.par)One could be interested to the prediction of marginal net survival
and marginal excess hazard of the individual with the same
characteristics as observed in the simuData.
#only add Surv variables (time_year and status) to have them in the new.data.
#They are not used for the prediction
#we could be interested to the prediction of net survival and excess hazard of the individual we the same characteristics that this one (age 50.5, race black)
predmar_mod1 <- predict(object = fit.estv1,
new.data = simuData,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
predmar_mod2 <- predict(object = fit.corrected1,
new.data = simuData,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
predmar_mod3 <- predict(object = fit.corrected2,
new.data = simuData,
times.pts = c(seq(0, 6, 0.1)),
baseline = FALSE)
par(mfrow = c(2, 1))
plot(
predmar_mod1,
what = "survival",
xlab = "time since diagnosis (year)",
ylab = "net survival",
ylim = c(0, 1),
main = "Estève Model"
)
par(new = TRUE)
plot(
predmar_mod2,
what = "survival",
xlab = "",
ylab = "",
ylim = c(0, 1),
lty = 2,
lwd = 2# main = "Touraine Model"
)
par(new = TRUE)
plot(
predmar_mod3,
what = "survival",
xlab = "",
ylab = "",
ylim = c(0, 1),
lty = 3,
lwd = 3#main = "Mba Model"
)
legend(
"bottomleft",
legend = c("Esteve Model",
"Touraine Model",
"Mba Model"),
lty = c(1, 2 , 3),
lwd = c(1, 2 , 3)
)
plot(
predmar_mod1,
what = "hazard",
xlab = "time since diagnosis (year)",
ylab = "excess hazard",
ylim = c(0, 0.30),
lty = 1
)
par(new = TRUE)
plot(
predmar_mod2,
what = "hazard",
xlab = "",
ylab = "",
ylim = c(0, 0.30),
lty = 2,
lwd = 2
)
par(new = TRUE)
plot(
predmar_mod3,
what = "hazard",
xlab = "",
ylab = "",
ylim = c(0, 0.30),
lty = 3,
lwd = 3
)
legend(
"topright",
legend = c("Esteve Model",
"Touraine Model",
"Mba Model"),
lty = c(1, 2 , 3),
lwd = c(1, 2 , 3)
)
par(old.par)GPL 3.0, for academic use.
We are grateful to the members of the CENSUR Survival Group for their helpful comments.