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Multivariate Event Times (mets)

Implementation of various statistical models for multivariate event history data doi:10.1007/s10985-013-9244-x. Including multivariate cumulative incidence models doi:10.1002/sim.6016, and bivariate random effects probit models (Liability models) doi:10.1016/j.csda.2015.01.014. Modern methods for survival analysis, including regression modelling (Cox, Fine-Gray, Ghosh-Lin, Binomial regression) with fast computation of influence functions. Restricted mean survival time regression and years lost for competing risks. Average treatment effects and G-computation. All functions can be used with clusters and will work for large data.

Installation

install.packages("mets")

The development version may be installed directly from github (requires Rtools on windows and development tools (+Xcode) for Mac OS X):

remotes::install_github("kkholst/mets", dependencies="Suggests")

or to get development version

remotes::install_github("kkholst/mets",ref="develop")

Citation

To cite the mets package please use one of the following references

Thomas H. Scheike and Klaus K. Holst (2022). A Practical Guide to Family Studies with Lifetime Data. Annual Review of Statistics and Its Application 9, pp. 47-69. doi: http://dx.doi.org/10.1146/annurev-statistics-040120-024253

Thomas H. Scheike and Klaus K. Holst and Jacob B. Hjelmborg (2013). Estimating heritability for cause specific mortality based on twin studies. Lifetime Data Analysis. http://dx.doi.org/10.1007/s10985-013-9244-x

Klaus K. Holst and Thomas H. Scheike Jacob B. Hjelmborg (2015). The Liability Threshold Model for Censored Twin Data. Computational Statistics and Data Analysis. http://dx.doi.org/10.1016/j.csda.2015.01.014

BibTeX:

@Article{,
  title = {A Practical Guide to Family Studies with Lifetime Data},
  author = {Thomas H. Scheike and Klaus K. Holst},
  year = {2014},
  volume = {9},
  pages = {47-69},
  journal = {Annual Review of Statistics and Its Application},
  doi = {10.1146/annurev-statistics-040120-024253},
}

@Article{,
  title={Estimating heritability for cause specific mortality based on twin studies},
  author={Scheike, Thomas H. and Holst, Klaus K. and Hjelmborg, Jacob B.},
  year={2013},
  issn={1380-7870},
  journal={Lifetime Data Analysis},
  doi={10.1007/s10985-013-9244-x},
  url={http://dx.doi.org/10.1007/s10985-013-9244-x},
  publisher={Springer US},
  keywords={Cause specific hazards; Competing risks; Delayed entry;
        Left truncation; Heritability; Survival analysis},
  pages={1-24},
  language={English}
}

@Article{,
  title={The Liability Threshold Model for Censored Twin Data},
  author={Holst, Klaus K. and Scheike, Thomas H. and Hjelmborg, Jacob B.},
  year={2015},
  doi={10.1016/j.csda.2015.01.014},
  url={http://dx.doi.org/10.1016/j.csda.2015.01.014},
  journal={Computational Statistics and Data Analysis}
}

Examples: Twins Polygenic modelling

First considering standard twin modelling (ACE, AE, ADE, and more models)

# simulated data with pairs of observations in twins on long #data format
set.seed(1)
d <- twinsim(1000, b1=c(1,-1), b2=c(), acde=c(1,1,0,1))
# Polygenic model with Additive genetic effects, and shared and individual environmental effects (ACE)
ace <- twinlm(y ~ 1, data=d, DZ="DZ", zyg="zyg", id="id")
ace
#>        Estimate Std. Error Z value  Pr(>|z|)
#> y     -0.019439   0.041817 -0.4649     0.642
#> sd(A)  0.902004   0.203739  4.4273 9.544e-06
#> sd(C)  1.137025   0.132852  8.5586 < 2.2e-16
#> sd(E)  1.728992   0.037408 46.2194 < 2.2e-16
#> 
#> MZ-pairs DZ-pairs 
#>     1000     1000 
#> 
#> Variance decomposition:
#>   Estimate 2.5%    97.5%  
#> A 0.15966  0.01867 0.30065
#> C 0.25370  0.13920 0.36820
#> E 0.58664  0.53677 0.63650
#> 
#> 
#>                          Estimate 2.5%    97.5%  
#> Broad-sense heritability 0.15966  0.01867 0.30065
#> 
#>                        Estimate 2.5%    97.5%  
#> Correlation within MZ: 0.41336  0.36229 0.46196
#> Correlation within DZ: 0.33353  0.27933 0.38561
#> 
#> 'log Lik.' -8779.953 (df=4)
#> AIC: 17567.91 
#> BIC: 17590.31
# An AE-model could be fitted as
ae <- twinlm(y ~ 1, data=d, DZ="DZ", zyg="zyg", id="id", type="ae")
# AIC
AIC(ae)-AIC(ace)
#> [1] 15.20656
# To adjust for the covariates we simply alter the formula statement
ace2 <- twinlm(y ~ x1+x2, data=d, DZ="DZ", zyg="zyg", id="id", type="ace")
 ## Summary/GOF
summary(ace2)
#>        Estimate Std. Error  Z value Pr(>|z|)
#> y     -0.026049   0.034844  -0.7476   0.4547
#> sd(A)  1.066060   0.072890  14.6256   <2e-16
#> sd(C)  0.980740   0.073569  13.3309   <2e-16
#> sd(E)  0.979980   0.021887  44.7736   <2e-16
#> y~x1   1.006963   0.021900  45.9807   <2e-16
#> y~x2  -0.993802   0.021962 -45.2512   <2e-16
#> 
#> MZ-pairs DZ-pairs 
#>     1000     1000 
#> 
#> Variance decomposition:
#>   Estimate 2.5%    97.5%  
#> A 0.37156  0.27300 0.47012
#> C 0.31446  0.22643 0.40250
#> E 0.31398  0.28381 0.34414
#> 
#> 
#>                          Estimate 2.5%    97.5%  
#> Broad-sense heritability 0.37156  0.27300 0.47012
#> 
#>                        Estimate 2.5%    97.5%  
#> Correlation within MZ: 0.68602  0.65467 0.71502
#> Correlation within DZ: 0.50024  0.45538 0.54257
#> 
#> 'log Lik.' -7449.697 (df=6)
#> AIC: 14911.39 
#> BIC: 14945

Examples: Twins Polygenic modelling time-to-events Data

In the context of time-to-events data we consider the “Liability Threshold model” with IPCW adjustment for censoring.

First we fit the bivariate probit model (same marginals in MZ and DZ twins but different correlation parameter). Here we evaluate the risk of getting cancer before the last double cancer event (95 years)

data(prt)
prt0 <-  force.same.cens(prt, cause="status", cens.code=0, time="time", id="id")
prt0$country <- relevel(prt0$country, ref="Sweden")
prt_wide <- fast.reshape(prt0, id="id", num="num", varying=c("time","status","cancer"))
prt_time <- subset(prt_wide,  cancer1 & cancer2, select=c(time1, time2, zyg))
tau <- 95
tt <- seq(70, tau, length.out=5) ## Time points to evaluate model in

b0 <- bptwin.time(cancer ~ 1, data=prt0, id="id", zyg="zyg", DZ="DZ", type="cor",
              cens.formula=Surv(time,status==0)~zyg, breaks=tau)
summary(b0)
#> 
#>                Estimate   Std.Err        Z   p-value    
#> (Intercept)   -1.348188  0.026276 -51.3086 < 2.2e-16 ***
#> atanh(rho) MZ  0.735992  0.087838   8.3789 < 2.2e-16 ***
#> atanh(rho) DZ  0.353023  0.068234   5.1737 2.295e-07 ***
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
#> 
#>  Total MZ/DZ Complete pairs MZ/DZ
#>  1994/3618   997/1809            
#> 
#>                            Estimate 2.5%    97.5%  
#> Tetrachoric correlation MZ 0.62672  0.51081 0.72024
#> Tetrachoric correlation DZ 0.33905  0.21584 0.45164
#> 
#> MZ:
#>                      Estimate 2.5%    97.5%  
#> Concordance          0.03504  0.02779 0.04409
#> Casewise Concordance 0.39458  0.31876 0.47584
#> Marginal             0.08880  0.08086 0.09743
#> Rel.Recur.Risk       4.44351  3.50521 5.38182
#> log(OR)              2.34131  1.87105 2.81157
#> DZ:
#>                      Estimate 2.5%    97.5%  
#> Concordance          0.01952  0.01449 0.02625
#> Casewise Concordance 0.21983  0.16667 0.28415
#> Marginal             0.08880  0.08086 0.09743
#> Rel.Recur.Risk       2.47556  1.81096 3.14016
#> log(OR)              1.23088  0.81020 1.65156
#> 
#>                          Estimate 2.5%    97.5%  
#> Broad-sense heritability 0.57533  0.25790 0.89276
#> 
#> 
#> Event of interest before time 95

Liability threshold model with ACE random effects structure

b1 <- bptwin.time(cancer ~ 1, data=prt0, id="id", zyg="zyg", DZ="DZ", type="ace",
           cens.formula=Surv(time,status==0)~zyg, breaks=tau)
summary(b1)
#> 
#>             Estimate  Std.Err        Z p-value    
#> (Intercept) -2.20664  0.16463 -13.4034  <2e-16 ***
#> log(var(A))  0.43260  0.39149   1.1050  0.2691    
#> log(var(C)) -1.98289  2.52342  -0.7858  0.4320    
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
#> 
#>  Total MZ/DZ Complete pairs MZ/DZ
#>  1994/3618   997/1809            
#> 
#>                    Estimate 2.5%     97.5%   
#> A                   0.57533  0.25790  0.89276
#> C                   0.05139 -0.20836  0.31114
#> E                   0.37328  0.26874  0.47782
#> MZ Tetrachoric Cor  0.62672  0.51081  0.72024
#> DZ Tetrachoric Cor  0.33905  0.21584  0.45164
#> 
#> MZ:
#>                      Estimate 2.5%    97.5%  
#> Concordance          0.03504  0.02779 0.04409
#> Casewise Concordance 0.39458  0.31876 0.47584
#> Marginal             0.08880  0.08086 0.09743
#> Rel.Recur.Risk       4.44351  3.50520 5.38182
#> log(OR)              2.34131  1.87104 2.81157
#> DZ:
#>                      Estimate 2.5%    97.5%  
#> Concordance          0.01952  0.01449 0.02625
#> Casewise Concordance 0.21983  0.16667 0.28415
#> Marginal             0.08880  0.08086 0.09743
#> Rel.Recur.Risk       2.47556  1.81096 3.14016
#> log(OR)              1.23088  0.81020 1.65156
#> 
#>                          Estimate 2.5%    97.5%  
#> Broad-sense heritability 0.57533  0.25790 0.89276
#> 
#> 
#> Event of interest before time 95

Examples: Twins Concordance for time-to-events Data


data(prt) ## Prostate data example (sim)

## Bivariate competing risk, concordance estimates
p33 <- bicomprisk(Event(time,status)~strata(zyg)+id(id),
                  data=prt, cause=c(2,2), return.data=1, prodlim=TRUE)
#> Strata 'DZ'
#> Strata 'MZ'

p33dz <- p33$model$"DZ"$comp.risk
p33mz <- p33$model$"MZ"$comp.risk

## Probability weights based on Aalen's additive model (same censoring within pair)
prtw <- ipw(Surv(time,status==0)~country+zyg, data=prt,
            obs.only=TRUE, same.cens=TRUE, 
            cluster="id", weight.name="w")

## Marginal model (wrongly ignoring censorings)
bpmz <- biprobit(cancer~1 + cluster(id), 
                 data=subset(prt,zyg=="MZ"), eqmarg=TRUE)

## Extended liability model
bpmzIPW <- biprobit(cancer~1 + cluster(id),
                    data=subset(prtw,zyg=="MZ"),
                    weights="w")
smz <- summary(bpmzIPW)

## Concordance
plot(p33mz,ylim=c(0,0.1),axes=FALSE, automar=FALSE,atrisk=FALSE,background=TRUE,background.fg="white")
axis(2); axis(1)

abline(h=smz$prob["Concordance",],lwd=c(2,1,1),col="darkblue")
## Wrong estimates:
abline(h=summary(bpmz)$prob["Concordance",],lwd=c(2,1,1),col="lightgray",lty=2)

Examples: Cox model, RMST

We can fit the Cox model and compute many useful summaries, such as restricted mean survival and standardized treatment effects (G-estimation). First estimating the standardized survival

 data(bmt)
 bmt$time <- bmt$time+runif(408)*0.001
 bmt$event <- (bmt$cause!=0)*1
 dfactor(bmt) <- tcell.f~tcell

 ss <- phreg(Surv(time,event)~tcell.f+platelet+age,bmt) 
 summary(survivalG(ss,bmt,50))
#> G-estimator :
#>       Estimate Std.Err   2.5%  97.5%    P-value
#> risk0   0.6539 0.02708 0.6008 0.7070 9.119e-129
#> risk1   0.5641 0.05973 0.4470 0.6811  3.600e-21
#> 
#> Average Treatment effect: difference (G-estimator) :
#>     Estimate Std.Err    2.5%   97.5% P-value
#> ps0 -0.08982 0.06293 -0.2132 0.03352  0.1535
#> 
#> Average Treatment effect: ratio (G-estimator) :
#> log-ratio: 
#>         Estimate  Std.Err       2.5%      97.5%   P-value
#> [ps0] -0.1477619 0.109562 -0.3624994 0.06697567 0.1774462
#> ratio: 
#>  Estimate      2.5%     97.5% 
#> 0.8626365 0.6959347 1.0692695 
#> 
#> Average Treatment effect:  survival-difference (G-estimator) :
#>       Estimate    Std.Err        2.5%     97.5%   P-value
#> ps0 0.08981829 0.06292811 -0.03351854 0.2131551 0.1534889
#> 
#> Average Treatment effect: 1-G (survival)-ratio (G-estimator) :
#> log-ratio: 
#>       Estimate   Std.Err        2.5%     97.5%   P-value
#> [ps0] 0.230711 0.1504459 -0.06415759 0.5255796 0.1251491
#> ratio: 
#>  Estimate      2.5%     97.5% 
#> 1.2594952 0.9378572 1.6914390

 sst <- survivalGtime(ss,bmt,n=50)
 plot(sst,type=c("survival","risk","survival.ratio")[1])

Based on the phreg we can also compute the restricted mean survival time and years lost (via Kaplan-Meier estimates). The function does it for all times at once and can be plotted as restricted mean survival or years lost at the different time horizons

 out1 <- phreg(Surv(time,cause!=0)~strata(tcell,platelet),data=bmt)
 
 rm1 <- resmean_phreg(out1, times=c(50))
 summary(rm1)
#>                     strata times    rmean se.rmean    lower    upper years.lost
#> tcell=0, platelet=0      0    50 20.48245 1.411055 17.89542 23.44348   29.51755
#> tcell=0, platelet=1      1    50 28.33071 2.196175 24.33733 32.97934   21.66929
#> tcell=1, platelet=0      2    50 22.74596 4.053717 16.04005 32.25544   27.25404
#> tcell=1, platelet=1      3    50 26.11565 4.230688 19.01112 35.87517   23.88435
 par(mfrow=c(1, 2))
 plot(rm1,se=1)
 plot(rm1,years.lost=TRUE,se=1)

For competing risks the years lost can be decomposed into different causes and is based on the integrated Aalen-Johansen estimators for the different strata

 ## years.lost decomposed into causes
drm1 <- cif_yearslost(Event(time,cause)~strata(tcell,platelet),data=bmt,times=50)
 par(mfrow=c(1,2)); plot(drm1,cause=1,se=1); title(main="Cause 1"); plot(drm1,cause=2,se=1); title(main="Cause 2")
 summary(drm1)
#> $estimate
#>                     strata times   intF_1    intF_2 se.intF_1 se.intF_2
#> tcell=0, platelet=0      0    50 21.36784  8.149711  1.476647  1.094520
#> tcell=0, platelet=1      1    50 12.97924  8.690047  2.047516  1.712441
#> tcell=1, platelet=0      2    50 12.64543 14.608610  4.089981  3.730259
#> tcell=1, platelet=1      3    50 11.80934 12.075008  3.673701  3.890207
#>                     total.years.lost lower_intF_1 upper_intF_1 lower_intF_2
#> tcell=0, platelet=0         29.51755    18.661106     24.46717     6.263606
#> tcell=0, platelet=1         21.66929     9.527297     17.68191     5.905902
#> tcell=1, platelet=0         27.25404     6.708487     23.83649     8.856404
#> tcell=1, platelet=1         23.88435     6.418453     21.72807     6.421784
#>                     upper_intF_2
#> tcell=0, platelet=0     10.60376
#> tcell=0, platelet=1     12.78669
#> tcell=1, platelet=0     24.09685
#> tcell=1, platelet=1     22.70487

Computations are again done for all time horizons at once as illustrated in the plot.

Examples: Cox model IPTW

We can fit the Cox model with inverse probability of treatment weights based on logistic regression. The treatment weights can be time-dependent and then multiplicative weights are applied (see details and vignette).

data(bmt)
bmt$time <- bmt$time+runif(408)*0.001
bmt$id <- seq_len(nrow(bmt))
bmt$event <- (bmt$cause!=0)*1
dfactor(bmt) <- tcell.f~tcell

fit <- phreg_IPTW(Surv(time,event)~tcell.f+cluster(id),data=bmt,treat.model=tcell.f~platelet+age) 
summary(fit)
#> 
#>    n events
#>  408    248
#> 
#>  408 clusters
#> coeffients:
#>           Estimate      S.E.   dU^-1/2 P-value
#> tcell.f1 -0.108497  0.199556  0.089653  0.5867
#> 
#> exp(coeffients):
#>          Estimate    2.5%  97.5%
#> tcell.f1  0.89718 0.60676 1.3266
head(IC(fit))
#>    tcell.f1
#> 1 -1.639241
#> 2 -1.669074
#> 3 -1.749761
#> 4 -1.745988
#> 5 -1.625416
#> 6 -1.793372

Examples: Competing risks regression, Binomial Regression

We can fit the logistic regression model at a specific time-point with IPCW adjustment

data(bmt); bmt$time <- bmt$time+runif(408)*0.001
# logistic regression with IPCW binomial regression 
out <- binreg(Event(time,cause)~tcell+platelet,bmt,time=50)
summary(out)
#>    n events
#>  408    160
#> 
#>  408 clusters
#> coeffients:
#>              Estimate   Std.Err      2.5%     97.5% P-value
#> (Intercept) -0.180371  0.126757 -0.428811  0.068068  0.1547
#> tcell       -0.418682  0.345438 -1.095729  0.258364  0.2255
#> platelet    -0.436959  0.240977 -0.909266  0.035349  0.0698
#> 
#> exp(coeffients):
#>             Estimate    2.5%  97.5%
#> (Intercept)  0.83496 0.65128 1.0704
#> tcell        0.65791 0.33430 1.2948
#> platelet     0.64600 0.40282 1.0360
head(IC(out))
#>           [,1]     [,2]    [,3]
#> [1,] -2.834084 1.633524 2.52025
#> [2,] -2.834084 1.633524 2.52025
#> [3,] -2.834084 1.633524 2.52025
#> [4,] -2.834084 1.633524 2.52025
#> [5,] -2.834084 1.633524 2.52025
#> [6,] -2.834084 1.633524 2.52025
 predict(out,data.frame(tcell=c(0,1),platelet=c(1,1)),se=TRUE)
#>        pred         se     lower     upper
#> 1 0.3503890 0.04848653 0.2553554 0.4454226
#> 2 0.2619201 0.06969710 0.1253138 0.3985265

Examples: Competing risks regression, Fine-Gray/Logistic link

We can fit the Fine-Gray model and the logit-link competing risks model (using IPCW adjustment). Starting with the logit-link model

data(bmt)
bmt$time <- bmt$time+runif(nrow(bmt))*0.01
bmt$id <- 1:nrow(bmt)
## logistic link  OR interpretation
 or=cifreg(Event(time,cause)~strata(tcell)+platelet+age,data=bmt,cause=1)
summary(or)
#> 
#>    n events
#>  408    161
#> 
#>  408 clusters
#> coeffients:
#>           Estimate      S.E.   dU^-1/2 P-value
#> platelet -0.454572  0.235415  0.187997  0.0535
#> age       0.390181  0.097675  0.083636  0.0001
#> 
#> exp(coeffients):
#>          Estimate    2.5%  97.5%
#> platelet  0.63472 0.40013 1.0069
#> age       1.47725 1.21987 1.7889
par(mfrow=c(1,2))
 ## to see baseline 
plot(or)

 # predictions 
nd <- data.frame(tcell=c(1,0),platelet=0,age=0)
pll <- predict(or,nd)
plot(pll)

Similarly, the Fine-Gray model can be estimated using IPCW adjustment

 ## Fine-Gray model
 fg=cifreg(Event(time,cause)~strata(tcell)+platelet+age,data=bmt,cause=1,propodds=NULL)
 summary(fg)
#> 
#>    n events
#>  408    161
#> 
#>  408 clusters
#> coeffients:
#>           Estimate      S.E.   dU^-1/2 P-value
#> platelet -0.424749  0.180772  0.187820  0.0188
#> age       0.341971  0.079862  0.086284  0.0000
#> 
#> exp(coeffients):
#>          Estimate    2.5%  97.5%
#> platelet  0.65393 0.45884 0.9320
#> age       1.40772 1.20375 1.6462
## baselines 
plot(fg)
nd <- data.frame(tcell=c(1,0),platelet=0,age=0)
pfg <- predict(fg,nd,se=1)
plot(pfg,se=1)

## influence functions of regression coefficients
head(iid(fg))
#>         platelet           age
#> [1,] 0.004953478  0.0001245648
#> [2,] 0.005348496 -0.0022341772
#> [3,] 0.006069271 -0.0087212019
#> [4,] 0.006043180 -0.0084186443
#> [5,] 0.004732097  0.0011839243
#> [6,] 0.006331457 -0.0121685409

and we can get standard errors for predictions based on the influence functions of the baseline and the regression coefficients (these are used in the predict function)

baseid <- iidBaseline(fg,time=40)
FGprediid(baseid,nd)
#>           pred     se-log     lower     upper
#> [1,] 0.2787465 0.23977109 0.1742272 0.4459672
#> [2,] 0.4506249 0.07265694 0.3908134 0.5195901

further G-estimation can be done

 dfactor(bmt) <- tcell.f~tcell
 fg1 <- cifreg(Event(time,cause)~tcell.f+platelet+age,bmt,cause=1,propodds=NULL)
 summary(survivalG(fg1,bmt,50))
#> G-estimator :
#>       Estimate Std.Err   2.5%  97.5%   P-value
#> risk0   0.4332 0.02749 0.3793 0.4871 6.331e-56
#> risk1   0.2726 0.05861 0.1577 0.3875 3.301e-06
#> 
#> Average Treatment effect: difference (G-estimator) :
#>     Estimate Std.Err   2.5%    97.5% P-value
#> ps0  -0.1606 0.06351 -0.285 -0.03609 0.01146
#> 
#> Average Treatment effect: ratio (G-estimator) :
#> log-ratio: 
#>        Estimate   Std.Err       2.5%       97.5%    P-value
#> [ps0] -0.463091 0.2211651 -0.8965667 -0.02961528 0.03627159
#> ratio: 
#>  Estimate      2.5%     97.5% 
#> 0.6293354 0.4079679 0.9708190

Examples: Marginal mean for recurrent events

We can estimate the expected number of events non-parametrically and get standard errors for this estimator

data(hfactioncpx12)
dtable(hfactioncpx12,~status)
#> 
#> status
#>    0    1    2 
#>  617 1391  124

gl1 <- recurrent_marginal(Event(entry,time,status)~strata(treatment)+cluster(id),hfactioncpx12,cause=1,death.code=2)
summary(gl1,times=1:5)
#> [[1]]
#>       new.time      mean         se   CI-2.5% CI-97.5% strata
#> 325          1 0.8737156 0.06783343 0.7503858 1.017315      0
#> 555          2 1.5718563 0.09572955 1.3949953 1.771140      0
#> 682          3 2.1184963 0.11385721 1.9066915 2.353829      0
#> 748          4 2.6815219 0.15451005 2.3951619 3.002118      0
#> 748.1        5 2.6815219 0.15451005 2.3951619 3.002118      0
#> 
#> [[2]]
#>       new.time      mean         se   CI-2.5%  CI-97.5% strata
#> 284          1 0.7815557 0.06908585 0.6572305 0.9293989      1
#> 499          2 1.4534055 0.10315606 1.2646561 1.6703258      1
#> 601          3 1.9240624 0.12165771 1.6998008 2.1779119      1
#> 645          4 2.3134997 0.14963892 2.0380418 2.6261880      1
#> 645.1        5 2.3134997 0.14963892 2.0380418 2.6261880      1
plot(gl1,se=1)

Examples: Ghosh-Lin for recurrent events

We can fit the Ghosh-Lin model for the expected number of events observed before dying (using IPCW adjustment and get predictions)

data(hfactioncpx12)
dtable(hfactioncpx12,~status)
#> 
#> status
#>    0    1    2 
#>  617 1391  124

gl1 <- recreg(Event(entry,time,status)~treatment+cluster(id),hfactioncpx12,cause=1,death.code=2)
summary(gl1)
#> 
#>     n events
#>  2132   1391
#> 
#>  741 clusters
#> coeffients:
#>             Estimate      S.E.   dU^-1/2 P-value
#> treatment1 -0.110404  0.078656  0.053776  0.1604
#> 
#> exp(coeffients):
#>            Estimate    2.5%  97.5%
#> treatment1  0.89547 0.76754 1.0447

## influence functions of regression coefficients
head(iid(gl1))
#>      treatment1
#> 1 -1.266428e-04
#> 2 -6.112340e-04
#> 3  2.885192e-03
#> 4  1.308207e-03
#> 5  5.404664e-05
#> 6  2.229380e-03

and we can get standard errors for predictions based on the influence functions of the baseline and the regression coefficients

 nd=data.frame(treatment=levels(hfactioncpx12$treatment),id=1)
 pfg <- predict(gl1,nd,se=1)
 summary(pfg,times=1:5)
#> $pred
#>              Lamt     Lamt     Lamt     Lamt     Lamt
#> strata0 0.8573256 1.592252 2.121181 2.635437 2.635437
#> strata0 0.7677110 1.425817 1.899458 2.359959 2.359959
#> 
#> $se.pred
#>       seLamt     seLamt    seLamt    seLamt    seLamt
#> 1 0.05719895 0.08818784 0.1096157 0.1429941 0.1429941
#> 2 0.05763288 0.09495475 0.1184567 0.1484200 0.1484200
#> 
#> $lower
#>              [,1]     [,2]     [,3]     [,4]     [,5]
#> strata0 0.7522383 1.428458 1.916860 2.369561 2.369561
#> strata0 0.6626698 1.251343 1.680916 2.086276 2.086276
#> 
#> $upper
#>              [,1]     [,2]     [,3]     [,4]     [,5]
#> strata0 0.9770936 1.774827 2.347281 2.931145 2.931145
#> strata0 0.8894025 1.624617 2.146415 2.669546 2.669546
#> 
#> $times
#> [1] 1 2 3 4 5
#> 
#> attr(,"class")
#> [1] "summarypredictrecreg"
 plot(pfg,se=1)

The influence functions of the baseline and regression coefficients at a specific time-point can be obtained

baseid <- iidBaseline(gl1,time=2)
dd <- data.frame(treatment=levels(hfactioncpx12$treatment),id=1)
GLprediid(baseid,dd)
#>          pred     se-log    lower    upper
#> [1,] 1.596065 0.05530215 1.432113 1.778786
#> [2,] 1.429231 0.06660096 1.254329 1.628521

and G-computation

 hfactioncpx12$age <- (50+rnorm(741)*4)[hfactioncpx12$id]

 GLout <- recreg(Event(entry,time,status)~treatment+age,data=hfactioncpx12,cause=1,death.code=2)
 summary(GLout)
#> 
#>     n events
#>  2132   1391
#> 
#>  2132 clusters
#> coeffients:
#>              Estimate       S.E.    dU^-1/2 P-value
#> treatment1 -0.1131085  0.0640898  0.0538154  0.0776
#> age         0.0086223  0.0079803  0.0066607  0.2799
#> 
#> exp(coeffients):
#>            Estimate    2.5%  97.5%
#> treatment1  0.89305 0.78763 1.0126
#> age         1.00866 0.99301 1.0246
 summary(survivalG(GLout,hfactioncpx12,time=4))
#> G-estimator :
#>       Estimate Std.Err  2.5% 97.5%    P-value
#> risk0    2.640  0.1203 2.404 2.876 1.067e-106
#> risk1    2.358  0.1165 2.130 2.586  3.838e-91
#> 
#> Average Treatment effect: difference (G-estimator) :
#>    Estimate Std.Err    2.5%   97.5% P-value
#> p1  -0.2824  0.1597 -0.5953 0.03059 0.07699
#> 
#> Average Treatment effect: ratio (G-estimator) :
#> log-ratio: 
#>        Estimate    Std.Err       2.5%      97.5%    P-value
#> [p1] -0.1131085 0.06408982 -0.2387222 0.01250527 0.07759015
#> ratio: 
#>  Estimate      2.5%     97.5% 
#> 0.8930538 0.7876336 1.0125838

Examples: Fixed time modelling for recurrent events

We can fit a log-link regression model at 2 years for the expected number of events observed before dying (using IPCW adjustment)

data(hfactioncpx12)

e2 <- recregIPCW(Event(entry,time,status)~treatment+cluster(id),hfactioncpx12,cause=1,death.code=2,time=2)
summary(e2)
#>    n events
#>  741   1052
#> 
#>  741 clusters
#> coeffients:
#>              Estimate   Std.Err      2.5%     97.5% P-value
#> (Intercept)  0.452430  0.060814  0.333236  0.571624  0.0000
#> treatment1  -0.078322  0.093560 -0.261696  0.105052  0.4025
#> 
#> exp(coeffients):
#>             Estimate    2.5%  97.5%
#> (Intercept)  1.57213 1.39548 1.7711
#> treatment1   0.92467 0.76974 1.1108
head(iid(e2))
#>            [,1]          [,2]
#> 1  1.959479e-04 -2.266440e-04
#> 2  2.237613e-03 -2.227140e-03
#> 3 -9.349773e-06  1.293789e-03
#> 4 -9.653029e-04  9.653029e-04
#> 5 -1.203962e-04  6.744236e-05
#> 6 -2.861359e-03  2.871831e-03

Examples: Cumulative Medical Cost

Estimate mean cumulative cost (see also vignette)

library(mets)
data(hfactioncpx12)
hf <- hfactioncpx12
hf$severity <- abs((5+rnorm(741)*2))[hf$id]

## marginal mean using formula  
outNZ <- recurrent_marginal(Event(entry,time,status)~strata(treatment)+cluster(id)
			 +marks(severity),hf,cause=1,death.code=2)
plot(outNZ,se=TRUE)
summary(outNZ,times=3)

For comparison we also compute the IPCW estimates at time 3, using the linear model, and note that they are identical. Standard errors are however based on different formula that are asymptotically equivalent, and we note that they are very similar.

outNZ3 <- recregIPCW(Event(entry,time,status)~-1+treatment+cluster(id)+marks(severity),data=hf,
		  cause=1,death.code=2,time=3,cens.model=~strata(treatment),model="lin")
summary(outNZ3)
head(iid(outNZ3))

We also apply the semiparametric proportional cost model with IPCW adjustment:

propNZ <- recreg(Event(entry,time,status)~treatment+marks(severity)+cluster(id),data=hf,cause=1,death.code=2)
summary(propNZ) 
plot(propNZ,main="Baselines")

Examples: Regression for RMST/Restricted mean survival for survival and competing risks using IPCW

RMST can be computed using the Kaplan-Meier (via phreg) and the for competing risks via the cumulative incidence functions, but we can also get these estimates via IPCW adjustment and then we can do regression

 ### same as Kaplan-Meier for full censoring model 
 bmt$int <- with(bmt,strata(tcell,platelet))
 out <- resmeanIPCW(Event(time,cause!=0)~-1+int,bmt,time=30,
                         cens.model=~strata(platelet,tcell),model="lin")
 estimate(out)
#>                        Estimate Std.Err  2.5% 97.5%   P-value
#> inttcell=0, platelet=0    13.61  0.8314 11.98 15.24 3.453e-60
#> inttcell=0, platelet=1    18.90  1.2694 16.42 21.39 3.717e-50
#> inttcell=1, platelet=0    16.19  2.4057 11.48 20.91 1.678e-11
#> inttcell=1, platelet=1    17.77  2.4532 12.96 22.58 4.391e-13
 head(iid(out))
#>             [,1] [,2] [,3] [,4]
#> [1,] -0.05341125    0    0    0
#> [2,] -0.05342611    0    0    0
#> [3,] -0.05343207    0    0    0
#> [4,] -0.05341706    0    0    0
#> [5,] -0.05342052    0    0    0
#> [6,] -0.05341259    0    0    0
 ## same as 
 out1 <- phreg(Surv(time,cause!=0)~strata(tcell,platelet),data=bmt)
 rm1 <- resmean_phreg(out1,times=30)
 summary(rm1)
#>                     strata times    rmean  se.rmean    lower    upper
#> tcell=0, platelet=0      0    30 13.60584 0.8314012 12.07012 15.33695
#> tcell=0, platelet=1      1    30 18.90350 1.2690639 16.57288 21.56188
#> tcell=1, platelet=0      2    30 16.19410 2.4002390 12.11140 21.65306
#> tcell=1, platelet=1      3    30 17.76830 2.4417528 13.57289 23.26053
#>                     years.lost
#> tcell=0, platelet=0   16.39416
#> tcell=0, platelet=1   11.09650
#> tcell=1, platelet=0   13.80590
#> tcell=1, platelet=1   12.23170
 
 ## competing risks years-lost for cause 1  
 out1 <- resmeanIPCW(Event(time,cause)~-1+int,bmt,time=30,cause=1,
                       cens.model=~strata(platelet,tcell),model="lin")
 estimate(out1)
#>                        Estimate Std.Err   2.5%  97.5%   P-value
#> inttcell=0, platelet=0   12.103  0.8507 10.436 13.770 6.168e-46
#> inttcell=0, platelet=1    6.883  1.1739  4.582  9.184 4.533e-09
#> inttcell=1, platelet=0    7.260  2.3529  2.648 11.871 2.033e-03
#> inttcell=1, platelet=1    5.779  2.0921  1.679  9.880 5.737e-03
 ## same as 
 drm1 <- cif_yearslost(Event(time,cause)~strata(tcell,platelet),data=bmt,times=30)
 summary(drm1)
#> $estimate
#>                     strata times    intF_1   intF_2 se.intF_1 se.intF_2
#> tcell=0, platelet=0      0    30 12.103113 4.291051 0.8506728 0.6160195
#> tcell=0, platelet=1      1    30  6.882894 4.213603 1.1738590 0.9055124
#> tcell=1, platelet=0      2    30  7.259595 6.546309 2.3529175 1.9699198
#> tcell=1, platelet=1      3    30  5.779287 6.452411 2.0920912 2.0811678
#>                     total.years.lost lower_intF_1 upper_intF_1 lower_intF_2
#> tcell=0, platelet=0         16.39416    10.545569    13.890702     3.238664
#> tcell=0, platelet=1         11.09650     4.927208     9.614821     2.765212
#> tcell=1, platelet=0         13.80590     3.846168    13.702396     3.629546
#> tcell=1, platelet=1         12.23170     2.842764    11.749182     3.429056
#>                     upper_intF_2
#> tcell=0, platelet=0     5.685405
#> tcell=0, platelet=1     6.420645
#> tcell=1, platelet=0    11.807030
#> tcell=1, platelet=1    12.141421

Examples: Average treatment effects (ATE) for survival or competing risks

We can compute ATE for survival or competing risks data for the probability of dying

 bmt$event <- bmt$cause!=0; dfactor(bmt) <- tcell~tcell
 brs <- binregATE(Event(time,cause)~tcell+platelet+age,bmt,time=50,cause=1,
      treat.model=tcell~platelet+age)
 summary(brs)
#>    n events
#>  408    160
#> 
#>  408 clusters
#> coeffients:
#>             Estimate  Std.Err     2.5%    97.5% P-value
#> (Intercept) -0.19901  0.13098 -0.45574  0.05771  0.1287
#> tcell1      -0.63788  0.35668 -1.33696  0.06120  0.0737
#> platelet    -0.34411  0.24604 -0.82634  0.13811  0.1619
#> age          0.43737  0.10727  0.22712  0.64762  0.0000
#> 
#> exp(coeffients):
#>             Estimate    2.5%  97.5%
#> (Intercept)  0.81954 0.63398 1.0594
#> tcell1       0.52841 0.26264 1.0631
#> platelet     0.70885 0.43765 1.1481
#> age          1.54862 1.25497 1.9110
#> 
#> Average Treatment effects (G-formula) :
#>             Estimate    Std.Err       2.5%      97.5% P-value
#> treat0     0.4288003  0.0275149  0.3748722  0.4827284  0.0000
#> treat1     0.2898471  0.0659033  0.1606789  0.4190153  0.0000
#> treat:1-0 -0.1389532  0.0717737 -0.2796272  0.0017208  0.0529
#> 
#> Average Treatment effects (double robust) :
#>            Estimate   Std.Err      2.5%     97.5% P-value
#> treat0     0.428211  0.027617  0.374084  0.482339  0.0000
#> treat1     0.250336  0.064792  0.123346  0.377325  0.0001
#> treat:1-0 -0.177876  0.070147 -0.315361 -0.040390  0.0112
 head(brs$riskDR.iid)
#>          iidriska      iidriska
#> [1,] -0.001159043 -3.524810e-05
#> [2,] -0.001201108  7.613126e-05
#> [3,] -0.001326534  3.362333e-04
#> [4,] -0.001320393  3.250252e-04
#> [5,] -0.001140791 -9.095525e-05
#> [6,] -0.001398307  4.597688e-04
 head(brs$riskG.iid)
#>        riskGa.iid    riskGa.iid
#> [1,] -0.001190759 -0.0001528426
#> [2,] -0.001242465  0.0001088968
#> [3,] -0.001355317  0.0006916069
#> [4,] -0.001350729  0.0006676909
#> [5,] -0.001164523 -0.0002838563
#> [6,] -0.001404170  0.0009471848

or the the restricted mean survival or years-lost to cause 1

 out <- resmeanATE(Event(time,event)~tcell+platelet,data=bmt,time=40,treat.model=tcell~platelet)
 summary(out)
#>    n events
#>  408    241
#> 
#>  408 clusters
#> coeffients:
#>              Estimate   Std.Err      2.5%     97.5% P-value
#> (Intercept)  2.852872  0.062472  2.730429  2.975315  0.0000
#> tcell1       0.021472  0.122886 -0.219381  0.262325  0.8613
#> platelet     0.303325  0.090731  0.125495  0.481155  0.0008
#> 
#> exp(coeffients):
#>             Estimate     2.5%   97.5%
#> (Intercept) 17.33750 15.33947 19.5958
#> tcell1       1.02170  0.80302  1.2999
#> platelet     1.35435  1.13371  1.6179
#> 
#> Average Treatment effects (G-formula) :
#>           Estimate  Std.Err     2.5%    97.5% P-value
#> treat0    19.26491  0.95910 17.38511 21.14472  0.0000
#> treat1    19.68305  2.22794 15.31637 24.04973  0.0000
#> treat:1-0  0.41813  2.41074 -4.30684  5.14310  0.8623
#> 
#> Average Treatment effects (double robust) :
#>           Estimate  Std.Err     2.5%    97.5% P-value
#> treat0    19.28397  0.95792 17.40649 21.16146  0.0000
#> treat1    20.34809  2.54086 15.36811 25.32808  0.0000
#> treat:1-0  1.06412  2.70957 -4.24654  6.37478  0.6945
 head(out$riskDR.iid)
#>         iidriska    iidriska
#> [1,] -0.05143041 0.005890787
#> [2,] -0.05144061 0.005890787
#> [3,] -0.05144470 0.005890787
#> [4,] -0.05143440 0.005890787
#> [5,] -0.05143678 0.005890787
#> [6,] -0.05143133 0.005890787
 head(out$riskG.iid)
#>       riskGa.iid  riskGa.iid
#> [1,] -0.05185784 -0.01866183
#> [2,] -0.05186812 -0.01866485
#> [3,] -0.05187225 -0.01866606
#> [4,] -0.05186186 -0.01866301
#> [5,] -0.05186425 -0.01866372
#> [6,] -0.05185876 -0.01866211

 out1 <- resmeanATE(Event(time,cause)~tcell+platelet,data=bmt,cause=1,time=40,
                    treat.model=tcell~platelet)
 summary(out1)
#>    n events
#>  408    157
#> 
#>  408 clusters
#> coeffients:
#>              Estimate   Std.Err      2.5%     97.5% P-value
#> (Intercept)  2.806167  0.069617  2.669721  2.942614  0.0000
#> tcell1      -0.374457  0.247756 -0.860051  0.111137  0.1307
#> platelet    -0.491638  0.164932 -0.814899 -0.168377  0.0029
#> 
#> exp(coeffients):
#>             Estimate     2.5%   97.5%
#> (Intercept) 16.54638 14.43594 18.9654
#> tcell1       0.68766  0.42314  1.1175
#> platelet     0.61162  0.44268  0.8450
#> 
#> Average Treatment effects (G-formula) :
#>           Estimate  Std.Err     2.5%    97.5% P-value
#> treat0    14.53031  0.95690 12.65481 16.40581   0.000
#> treat1     9.99195  2.37789  5.33137 14.65253   0.000
#> treat:1-0 -4.53836  2.57483 -9.58494  0.50822   0.078
#> 
#> Average Treatment effects (double robust) :
#>             Estimate    Std.Err       2.5%      97.5% P-value
#> treat0     14.512256   0.957862  12.634880  16.389632  0.0000
#> treat1      9.362018   2.416771   4.625234  14.098802  0.0001
#> treat:1-0  -5.150238   2.597631 -10.241501  -0.058975  0.0474

Here event is 0/1 thus leading to restricted mean and cause taking the values 0,1,2 produces regression for the years lost due to cause 1.

Examples: While Alive estimands for recurrent events

We consider an RCT and aim to describe the treatment effect via while alive estimands

data(hfactioncpx12)

dtable(hfactioncpx12,~status)
#> 
#> status
#>    0    1    2 
#>  617 1391  124
dd <- WA_recurrent(Event(entry,time,status)~treatment+cluster(id),hfactioncpx12,time=2,death.code=2)
summary(dd)
#> While-Alive summaries:  
#> 
#> RMST,  E(min(D,t)) 
#>            Estimate Std.Err  2.5% 97.5% P-value
#> treatment0    1.859 0.02108 1.817 1.900       0
#> treatment1    1.924 0.01502 1.894 1.953       0
#>  
#>                           Estimate Std.Err    2.5%    97.5% P-value
#> [treatment0] - [treat.... -0.06517 0.02588 -0.1159 -0.01444  0.0118
#> 
#>  Null Hypothesis: 
#>   [treatment0] - [treatment1] = 0 
#> mean events, E(N(min(D,t))): 
#>            Estimate Std.Err  2.5% 97.5%   P-value
#> treatment0    1.572 0.09573 1.384 1.759 1.375e-60
#> treatment1    1.453 0.10315 1.251 1.656 4.376e-45
#>  
#>                           Estimate Std.Err    2.5%  97.5% P-value
#> [treatment0] - [treat....   0.1185  0.1407 -0.1574 0.3943     0.4
#> 
#>  Null Hypothesis: 
#>   [treatment0] - [treatment1] = 0 
#> _______________________________________________________ 
#> Ratio of means E(N(min(D,t)))/E(min(D,t)) 
#>    Estimate Std.Err   2.5%  97.5%   P-value
#> p1   0.8457 0.05264 0.7425 0.9488 4.411e-58
#> p2   0.7555 0.05433 0.6490 0.8619 5.963e-44
#>  
#>             Estimate Std.Err     2.5%  97.5% P-value
#> [p1] - [p2]  0.09022 0.07565 -0.05805 0.2385   0.233
#> 
#>  Null Hypothesis: 
#>   [p1] - [p2] = 0 
#> _______________________________________________________ 
#> Mean of Events per time-unit E(N(min(D,t))/min(D,t)) 
#>        Estimate Std.Err   2.5%  97.5%   P-value
#> treat0   1.0725  0.1222 0.8331 1.3119 1.645e-18
#> treat1   0.7552  0.0643 0.6291 0.8812 7.508e-32
#>  
#>                     Estimate Std.Err    2.5%  97.5% P-value
#> [treat0] - [treat1]   0.3173  0.1381 0.04675 0.5879 0.02153
#> 
#>  Null Hypothesis: 
#>   [treat0] - [treat1] = 0

dd <- WA_recurrent(Event(entry,time,status)~treatment+cluster(id),hfactioncpx12,time=2,
           death.code=2,trans=.333)
summary(dd,type="log")
#> While-Alive summaries, log-scale:  
#> 
#> RMST,  E(min(D,t)) 
#>            Estimate  Std.Err   2.5%  97.5% P-value
#> treatment0   0.6199 0.011340 0.5977 0.6421       0
#> treatment1   0.6543 0.007807 0.6390 0.6696       0
#>  
#>                           Estimate Std.Err     2.5%     97.5% P-value
#> [treatment0] - [treat.... -0.03446 0.01377 -0.06145 -0.007478 0.01231
#> 
#>  Null Hypothesis: 
#>   [treatment0] - [treatment1] = 0 
#> mean events, E(N(min(D,t))): 
#>            Estimate Std.Err   2.5%  97.5%   P-value
#> treatment0   0.4523 0.06090 0.3329 0.5716 1.119e-13
#> treatment1   0.3739 0.07097 0.2348 0.5130 1.376e-07
#>  
#>                           Estimate Std.Err    2.5%  97.5% P-value
#> [treatment0] - [treat....  0.07835 0.09352 -0.1049 0.2616  0.4022
#> 
#>  Null Hypothesis: 
#>   [treatment0] - [treatment1] = 0 
#> _______________________________________________________ 
#> Ratio of means E(N(min(D,t)))/E(min(D,t)) 
#>    Estimate Std.Err    2.5%    97.5%   P-value
#> p1  -0.1676 0.06224 -0.2896 -0.04563 7.081e-03
#> p2  -0.2804 0.07192 -0.4214 -0.13947 9.651e-05
#>  
#>             Estimate Std.Err     2.5%  97.5% P-value
#> [p1] - [p2]   0.1128 0.09511 -0.07361 0.2992  0.2356
#> 
#>  Null Hypothesis: 
#>   [p1] - [p2] = 0 
#> _______________________________________________________ 
#> Mean of Events per time-unit E(N(min(D,t))/min(D,t)) 
#>        Estimate Std.Err    2.5%   97.5%   P-value
#> treat0  -0.3833 0.04939 -0.4801 -0.2865 8.487e-15
#> treat1  -0.5380 0.05666 -0.6491 -0.4270 2.191e-21
#>  
#>                     Estimate Std.Err     2.5%  97.5% P-value
#> [treat0] - [treat1]   0.1548 0.07517 0.007459 0.3021 0.03948
#> 
#>  Null Hypothesis: 
#>   [treat0] - [treat1] = 0

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install.packages('mets')

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Version

1.3.11

License

Apache License (== 2.0)

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Maintainer

Klaus Holst

Last Published

July 1st, 2026

Functions in mets (1.3.11)

bptwin

Liability model for twin data
calgb8923

CALGB 8923, twostage randomization SMART design
casewise

Estimate Casewise Concordance from prodlim Objects
binregTSR

Two-Stage Randomization for Survival or Competing Risks Data
cif

Cumulative Incidence with Robust Standard Errors
cif_yearslost

Restricted Mean Time Lost for Competing Risks
binregStrata

Binomial Regression with Stratified Pseudo-Values and Censoring Adjustment
casewise_bin

Casewise Concordance from Concordant/Discordant Counts
rr_cif

Non-parametric Cumulative Incidence Functions
biprobit

Bivariate Probit model
bicomprisk

Estimation of Concordance in Bivariate Competing Risks Data
cor_cif

Cross-odds-ratio, OR or RR risk regression for competing risks
cumoddsreg

Cumulative Odds Regression for Discrete Time Data
concordanceCor

Concordance Computes concordance and casewise concordance
binreg_IPTW

IPTW logistic regression, Inverse Probabibilty of Treatment Weighted binreg
count_history

Compute cumulative event counts as time-dependent covariates
dermalridges

Dermal ridges data (families)
drop.specials

Remove Special Terms from a Formula
dsort

Sort data frame
bmt

The Bone Marrow Transplant Data
dtransform

Transform that allows condition
estimate.binregCV

Joint estimate across CV models for a binregCV object
fast.pattern

Fast pattern
fast.reshape

Fast reshape
cifreg

Cumulative Incidence Function (CIF) Regression
cifregFG

Fine-Gray Cumulative Incidence Function Regression
daggregate

aggregating for for data frames
dtable

tables for data frames
dspline

Simple linear spline
dby

Calculate summary statistics grouped by
dlag

Lag operator
dprint

list, head, print, tail
extendCums

Extend Cumulative Hazard Functions to Common Time Range
divide_conquer

Split a data set and run function
eventpois

Extract survival estimates from lifetable analysis
force.same.cens

Force Same Censoring Within Clusters
blocksample

Block sampling
fast.approx

Fast approximation
cluster_index

Finds subjects related to same cluster
brier_binreg

Cross-validated Brier score for competing risks, RMST and RMTL regression using stratified leave-fold-out fits (binregStrata)
diabetes

The Diabetic Retinopathy Data
dermalridgesMZ

Dermal ridges data (monozygotic twins)
haplo_surv_discrete

Discrete Time-to-Event Haplotype Analysis
coarse_clust

Coarsen Cluster Identifiers
event_split

event_split (SurvSplit).
drelevel

relev levels for data frames
dcut

Cutting, sorting, rm (removing), rename for data frames
dreg

Regression for data frames with dutility call
dcor

summary, tables, and correlations for data frames
gof.phreg

Goodness-of-Fit for Cox PH Regression (Proportionality)
faster.reshape

Fast Reshape from Long to Wide Format
mediatorSurv

Mediation analysis in survival context
ilap

Inverse Laplace Transform Helper
folds

Generate Random Fold Indices for Cross-Validation
iidBaseline

Influence Functions or IID Decomposition of Baseline
event_split2

Event split with two time-scales, time and gaptime
interval_logitsurv_discrete

Discrete Time-to-Event Analysis with Interval Censoring
plack_cif

plack Computes concordance for or.cif based model, that is Plackett random effects model
hfactioncpx12

hfaction, subset of block randomized study HF-ACtion from WA package
medweight

Computes mediation weights
plot.phreg

Plotting the baselines of stratified Cox
fast.cluster

Fast Cluster Index Conversion
logitSurv

Proportional Odds Survival Model
lifetable.matrix

Life table
ipw

Inverse Probability of Censoring Weights
mets-package

mets: Analysis of Multivariate Event Times
mets-simulation

Simulation Helper Functions
grouptable

Create Group Contingency Table from Clustered Data
ipw2

Inverse Probability of Censoring Weights
jumptimes

Extract Event (Jump) Times
familycluster_index

Finds all pairs within a cluster (family)
familyclusterWithProbands_index

Finds all pairs within a cluster (famly) with the proband (case/control)
prob_exceed_recurrent

Estimate the probability of exceeding k recurrent events by time t
robust.basehaz.phreg

Robust Baseline Hazard Standard Errors
prt

Prostate data set
mena

Menarche data set
melanoma

The Melanoma Survival Data
np

np data set
predict.mlogit

Predictions from Multinomial Regression
haplo

haplo fun data
predict.phreg

Predictions from Proportional Hazards Model
rcrisk

Simulation of Piecewise constant hazard models with two causes (Cox).
recreg

Recurrent Events Regression with Terminal Event
sim_phreg

Simulation of Output from Cox Model
km

Kaplan-Meier with Robust Standard Errors
gofM_phreg

Goodness-of-Fit for Cox Covariates (Model Matrix)
gofZ_phreg

Goodness-of-Fit for Cox Covariates (Linearity)
mets.options

Set global options for mets
phreg_IPTW

IPTW Cox Regression (Inverse Probability of Treatment Weighted)
recurrent_marginal

Marginal mean estimation for recurrent events with a terminal event
multcif

Multivariate Cumulative Incidence Function example data set
phreg

Fast Cox Proportional Hazards Regression
mlogit

Multinomial Regression Based on phreg
recregIPCW

IPCW Estimator for Recurrent Events
lifecourse

Life-course plot
sim_ClaytonOakes

Simulate from the Clayton-Oakes frailty model
rweibullcox

Simulate observations from a Weibull distribution
sim_multistateII

Illness-Death Competing Risks with Two Causes of Death
survival-helpers

Survival Twostage Helpers
phreg_rct

Lu-Tsiatis More Efficient Log-Rank for Randomized Studies with Baseline Covariates
migr

Migraine data
survivalG

G-Estimator for Cox and Fine-Gray Models
sim_phregs

Simulation of Cause-Specific Cox Models
sim_recurrentTS

Simulate recurrent events from a two-stage model with structured gamma frailties
sim_recurrentII

Simulate recurrent events with two event types and a terminal event
plot_twin

Scatter plot function
resmeanIPCW

Restricted IPCW Mean for Censored Survival Data
pmvn

Multivariate normal distribution function
random_cif

Random effects model for competing risks data
ratioATE

Ratio of Average Treatment Effects
resmean_phreg

Restricted Mean for Stratified Kaplan-Meier or Cox Model
summaryGLM

Reporting OR (exp(coef)) from glm with binomial link and glm predictions
p11_binomial_twostage_RV

Concordance Probability from Twostage Model
twinbmi

BMI data set
summary.cor

Summary for dependence models for competing risks
sim_multistate

Simulation of Illness-Death Model
sim_cif

Simulation of Output from Cumulative Incidence Regression Model
print.summary_binregCV_multi

Print method for summary_binregCV_multi objects
test_marginalMean

Pepe-Mori Test for Marginal Mean Comparison
tetrachoric

Estimate parameters from odds-ratio
phreg_weibull

Weibull-Cox regression
print.casewise

prints Concordance test
twinstut

Stutter data set
sim_recurrent

Simulate recurrent events with a single event type and a terminal event
twostageMLE

Twostage Survival Model Fitted by Pseudo MLE
twinlm

Classic twin model for quantitative traits
sim_recurrent_ts

Simulate recurrent events from a two-stage Cox or Ghosh-Lin model
strata-numeric

Stratified Cumulative and Summary Operations
twinsim

Simulate twin data
test_conc

Compare Two Concordance Estimates
test_logrankRecurrent

Logrank-type test for comparing recurrent event marginal means between groups
rchaz

Simulation of Piecewise Constant Hazard Model (Cox)
reexports

Objects exported from other packages
rchazl

Multiple Cause Piecewise Constant Hazard Simulation
sim_ClaytonOakesWei

Simulate from the Clayton-Oakes frailty model
resmeanATE

Average Treatment Effect for Restricted Mean Time
survival_twostage

Twostage Survival Model for Multivariate Survival Data
surv_boxarea

Bivariate Survival Data on Rectangular Regions
summaryTimeobject

Summarize a Time-Varying Estimate with Confidence Bands
summary.binregCV_list

Summary method for binregCV_list objects
sim_GLcox

Simulation of Two-Stage Recurrent Events Data
summary.binregCV

Summary method for binregCV objects
ttpd

ttpd discrete survival data on interval form
tie_breaker

Break ties in event times for recurrent event data
test_casewise

Test for Independence Using Casewise Concordance
twostageREC

Fitting of Two-Stage Recurrent Events Random Effects Model
IC.phreg

Influence Functions for phreg objects
CPH_HPN_CRBSI

Rates for HPN program for patients of Copenhagen Cohort
ClaytonOakes

Clayton-Oakes model with piece-wise constant hazards
Dbvn

Derivatives of the bivariate normal cumulative distribution function
IC.binreg

Influence curve components for binomial regression ATE
Event

Event history object
aalenMets

Fast Additive Hazards Model with Robust Standard Errors
ACTG175

ACTG175, block randomized study from speff2trial package
Grandom_cif

Additive Random effects model for competing risks data for polygenetic modelling
WA_reg

While-Alive Regression for Recurrent Events
WA_recurrent

While-Alive Estimands for Recurrent Events
TRACE

The TRACE study group of myocardial infarction
binregATE

Average Treatment Effect for Censored Competing Risks Data using Binomial Regression
LinSpline

Simple linear spline
binregCasewise

Estimate Casewise Concordance Using Binomial Regression
binregG

G-Estimator for Binomial Regression Model (Standardized Estimates)
binregRatio

Percentage of Years Lost Due to a Cause Regression
binomial_twostage

Fits Clayton-Oakes or bivariate Plackett (OR) models for binary data using marginals that are on logistic form. If clusters contain more than two times, the algoritm uses a compososite likelihood based on all pairwise bivariate models.
binreg

Binomial Regression for Censored Competing Risks Data