I'm currently looking into survival analysis regression models and can't quite wrap my head around the following:

Say I want to model time to occurrence of a cardiovascular event and use age (as opposed to follow-up time) as the underlying time scale. It seems clear to me that it doesn't make sense to include age as a covariate in the model, but what about (2-way) interaction terms between age and another risk factor, say smoking or blood pressure? Would it make sense to include such interaction terms as covariates (also in light of the usual advice to always include both of an interaction's constituent main effects, which in this case wouldn't seem to make much sense for the age main effect)?

Also, assuming it would be possible to include such interaction terms, should I treat age as a time-varying covariate (i.e., re-calculate the hazard in different years of the follow-up based on different values of age) or should I use the baseline age value only?


EDIT: As an example of the age * covariate interaction problem described above, consider the model described in this quote from the supplementary material of Hajifathalian et al. (2015) (excluding the references made in this quote):

We used sex- and cohort-stratified Cox proportional hazards regression to estimate the coefficients of the risk function, similar to previous cohort pooling projects. The risk predictors (smoking, diabetes, serum total cholesterol and systolic blood pressure) were measured at baseline. Participants’ age was used as the time scale, which allows age-specific cardiovascular disease (CVD) rates to vary across cohorts, and hence across populations to which the risk score is applied. This parameterization allows the risk equation to be recalibrated to each country, and each sex and age group within it, by replacing the age-sex-specific CVD rates from the pooled cohorts with those from the application country. We included interaction terms between all risk factors and age and, as described in the main paper, between sex and diabetes, and sex and smoking based on previous evidence.

The Cox model is given as:

$\lambda_i(t)=\lambda_{0,k}(t)exp(\sum^4_{l=1}\beta_lX_{i,l}+\sum^4_{l=1}\delta_ltX_{i,l}+\sum^4_{l=3}\gamma_lsex_iX_{i,l}$ (1)

where subscript $i$ denotes individual participants in the cohorts; $k$ denotes sex-cohort combination; $l$ denotes risk factors in the risk prediction equation (1: systolic blood pressure, 2: total cholesterol, 3: diabetes, and 4: smoking); $t$ denotes age in years; $X_{i,l}$ is the level of the risk factor $l$ for individual $i$ at baseline; $\beta_l$ is the log hazard ratio (HR) for the main effect of each risk factor, $\delta_l$ is the coefficient for linear interaction between risk factor $l$ and age, and $\gamma_l$ is the coefficient for interaction between diabetes and smoking, and sex; and $\lambda_{0,k}(t)$ is the age-specific hazard of CVD at the average level of risk factors for participants of sex-cohort $k$. $\lambda_{0,k}(t)$ is conceptually equivalent to an age-specific version of the $S_0(t)$ parameter in the specification used by D’Agostino and colleagues in the Framingham Risk Score. This formulation of the risk prediction equation does not need a coefficient for age although it includes interaction terms between age and other risk factors as described below.


2 Answers 2


Bendix Carstensen has a nice presentation in which he shows how this can be accomplished by splitting individual follow up time into small pieces and use a Poisson model for the rates thereby using the time scale (in your case age) as a covariate rather than part of the outcome. If you use R, the Epi package contains the tools you need.

Another option is to extend the Cox model to include time-dependent coefficients. See this vignette for the survival package in R. In that vignette it is also explained why it is not appropriate to include a covariate * age follow-up time interaction directly in the Cox model.

EDIT: Removed the bit about baseline age. That would of course not make sense with age as the time scale. Typed a bit too fast...

EDIT 2: Yes, the age * covariate interaction is an example of a time dependent coefficient and one of the ways for assessing the proportional hazards assumption.

As for the paper, it is possible that the critisism could apply. I can't find any info that the authors allowed for time-dependent coefficients. Including the age * covariate interaction is certainly possible, and R prints a warning message but estimates the coefficients. See the example below which is very inspired by the vignette mentioned above.


## Use age as the time scale
## age * karno in the model
fit1 <- coxph(Surv(age, age + time, status == 1) ~ trt + celltype + karno + age:karno, data = veteran)
Warning message:
In coxph(Surv(age, age + time, status == 1) ~ trt + celltype + age *  :
  a variable appears on both the left and right sides of the formula

## karno as a time-dependent coefficient, simple interaction similar to fit1
fit2 <- coxph(Surv(age, age + time, status == 1) ~ trt + celltype + karno + tt(karno),
          tt = function(x, t, ...) x * t, data = veteran)

## Coefficients from fit1
> fit1
coxph(formula = Surv(age, age + time, status == 1) ~ trt + celltype + 
karno + age:karno, data = veteran)

                       coef exp(coef)  se(coef)     z       p
trt                2.59e-01  1.30e+00  2.05e-01  1.26  0.2072
celltypesmallcell  8.32e-01  2.30e+00  2.73e-01  3.05  0.0023
celltypeadeno      1.17e+00  3.21e+00  2.95e-01  3.95 7.8e-05
celltypelarge      3.95e-01  1.48e+00  2.83e-01  1.39  0.1633
karno             -3.33e-02  9.67e-01  1.07e-02 -3.10  0.0020
karno:age          4.75e-05  1.00e+00  1.77e-04  0.27  0.7890

Likelihood ratio test=62  on 6 df, p=1.75e-11
n= 137, number of events= 128

## Coefficients from fit2

> fit2
coxph(formula = Surv(age, age + time, status == 1) ~ trt + celltype + 
karno + tt(karno), data = veteran, tt = function(x, t, ...) x * 

                       coef exp(coef)  se(coef)     z       p
trt                1.70e-01  1.19e+00  2.04e-01  0.84 0.40333
celltypesmallcell  9.08e-01  2.48e+00  2.75e-01  3.30 0.00097
celltypeadeno      1.22e+00  3.40e+00  3.00e-01  4.08 4.5e-05
celltypelarge      4.04e-01  1.50e+00  2.83e-01  1.42 0.15422
karno             -4.69e-02  9.54e-01  8.33e-03 -5.63 1.8e-08
tt(karno)          1.15e-04  1.00e+00  4.71e-05  2.45 0.01443

Likelihood ratio test=68.2  on 6 df, p=9.45e-13
n= 137, number of events= 128

Note the difference in the estimated coefficients. Reading the vignette again I see that section 4.2 deals with follow-up time * covariate interaction and not necessarily age * covariate interaction. But I think the example illustrates that results can be misleading when not properly allowing for time-dependent coefficients.

Hope this helps!

  • $\begingroup$ Thanks for the interesting links! So am I right to assume that the problem of age * covariate interactions can be understood as a time dependent coefficient problem, and that by your statement "it is also explained why it is not appropriate to include a covariate * age interaction directly" you are referring to the mistake which is described in the first paragraphs of section 4.2 of the vignette? Would you say this criticism also applies to the method in the paper I quoted in my (now edited) original post? $\endgroup$
    – h_bauer
    Jun 17, 2016 at 13:58
  • $\begingroup$ I have updated the answer and added an example which compares a model with age * covariate interaction and a model which properly accounts for time-dependent coefficients $\endgroup$
    – ErikL
    Jun 20, 2016 at 9:47

I would argue that it does not make sense, at least not in a Cox model.

The reason is that with the main effect of age $t$, the hazard function would be \begin{align} h_i(t) &= h_0(t) \exp(\beta x_i + \gamma x_i t + t) \\ &=h_0(t) \log(t) \exp(\beta x_i + \gamma x_i t) \\ &= h_0'(t) \exp(\beta x_i + \gamma x_i t) \end{align}

Since $h_0$ is non-parametric in the Cox model, the "main effect" of age is confounded with the baseline effect of age.

Now if age is your time scale, then age at baseline is 0 for everybody. So that's a pointless covariate. If your time scale is time since randomisation or something like that, then the age at baseline is different for the individuals in the data set and it makes sense to include it, as time constant (hence age at baseline).

Now say that your time scale is age since randomisation and you include age as a time-dependent covariate. You have $age_i(t)$ age at time $t$. The hazard you estimate is then \begin{align} h_i(t) &= h_0(t) \exp(\beta x_i + \gamma age_i(t)) \\ &= h_0(t) \exp(\beta x_i + \gamma(t + age_i(0)) \\ &= h_0(t) \exp(\gamma t) \exp(\beta x_i + \gamma age_i(0)) \end{align} As you can see, the hazard ratio of two individuals will depend on age only through the age at baseline, since the first term with $\exp(\gamma t)$ cancels out.

It is very useful to write down the hazard and think about what you want to estimate when include time-varying aspects outside the baseline hazard. That is, if you want to model the hazard in a proportional hazards model

  • $\begingroup$ Thanks for the detailed reply, and pointing out that the age main effect coefficient will be absorbed into the baseline hazard function (if I understood correctly). However, as it appears to me, this doesn't seem to solve the problem of age * covariate interactions I described. In fact, in your first equation, this is confirmed by the fact that only t (and its coefficient, which is missing from the equation) gets absorbed into h0(t), but not gamma * x[i] * t. $\endgroup$
    – h_bauer
    Jun 17, 2016 at 13:55
  • $\begingroup$ Indeed, you can have the covariate by time interaction in the model. My point is that you should not include the main effect of the time variable. $\endgroup$
    – Theodor
    Jun 17, 2016 at 22:27

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