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Parametric Survival Models (ch. 7)

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Title: Parametric Survival Models (ch. 7)


1
Parametric Survival Models (ch. 7)
  • notations
  • Y survival variable Ssurvival function,
    fdensity (pdf) Fcdf1-S. All these functios
    involve the unknown parameter (or vector of
    parameters) theta (??. The 2 examples well
    consider are
  • exponential with
  • Weibull with

2
  • The maximum likelihood estimator of
  • and is a function of the
    observed Ys which maximizes the likelihood,
    L(???a constant multiple of the joint
    distribution of the observed data. So theta-hat
    maximizes L over all possible values of theta
  • the mathematical method is discussed at the top
    of page 120 - note that usually the log of the
    likelihood is maximized

3
  • Ill list some of the important results given in
    this section
  • define the score function as the derivative of
    the log-likelihood
  • define Fishers information as
  • then
  • at the bottom of p. 120 and top of p.121, the
    method of actually finding maximum likelihood
    estimators is discussed and it is shown that

4
  • Then hypothesis tests about ? can be based on any
    of the 3 statistics below. To test use one of
  • Wald test
  • LR test
  • Score test

5
  • Lets use the LR test to compare models (see p.
    179-180) - use the notation there
  • The likelihood ratio test of the current model is
  • The likelihood ratio test of the full model is
  • Their difference (subtract the full minus the
    current likelihoods) is asymptotically chi-square
    with q d.f. and may be used to test whether the
    additional q parameters in the full model are
    zero.
  • This difference is called the deviance

6
  • Now go to p.127, the exponential model
  • Def. 7.2 Y ?(???? if the pdf of Y is
  • here ? is the gamma function. Since ??1)1,, the
    exponential model is a special case of the gamma
    for ??1.
  • The chi-square distribution is also a special
    case of the gamma.

7
  • here are some other relationships(Lemma 7.1 on
    page 128)
  • now go to page 131 Maximum likelihood under Type
    I censoring . Suppose we have a survival
    variable Y exp(?), subject to Type I censoring.
    Beta is the MTTF and we may use maximum
    likelihood methods to estimate it(p.131 and 132)

8
  • Maximizing the likelihood equation gives the
  • MLE of ? as
  • so we may use this to construct a 95 CI for the
    MTTF

9
  • In the Weibull model we assume Y W(???? subject
    to Type I censoring. Or we may work with the logs
    of the survival data, Xloge(Y).
  • The Xs have the 2-parameter (here u and b)
    extreme value distribution
  • The survival function is given by
  • The original Weibull parameters can be estimated
    if u and b are estimated by u-hat and b-hat

10
  • So, now go over example 7.4. Use SAS to read in
    the switch failure time data on p.135 (see
    website). Then get estimates of the the Weibull
    parameters for both the log-transformed and
    non-transformed data - use PROC LIFEREG - dont
    forget
  • Notice that we may use the NOLOG option in the
    MODEL statement to not take logs of the data
  • proc lifereg dataswitch model ucensor(0)
    /nolog distweibull title 'Modeling ulog(Y) w/
    NOLOG option'
  • proc lifereg dataswitch model ycensor(0)
    /distweibull
  • title 'Modeling non-transformed Y' run quit
  • Return to Section 4.4 (p. 61-62) and use SAS to
    get a probability plot (formula 4.4) of this
    data

11
  • Read section 8.5 on Diagnostics for choosing
    between models
  • Recall the empirical
  • survivor plot
  • Diagnostic 1 Plot the empirical survivor plots
    for each of the groups in a classification
    variable on the same plot. They should be
    location shifted versions of the baseline
    survival function when an accelerated lifetimes
    model is appropriate
  • Diagnostic 2 Compare the standard deviations of
    the data in each group (or when enough data
    points permits, the s.d.s at each covariate
    level). This allows us to check the constancy of
    sigma in the AFT model.
  • Diagnostic 3 Plot to see if they are
    parallel - if so, the proportional hazards is
    correct

12
  • Diagnostic 3 (continued) These curves will be
    straight lines when log(y) is plotted as the
    x-coordinate (rather than y) and the Weibull
    model fits the data well.
  • Go over Example 8.3 and use either R or SAS (or
    both!) to reproduce the diagnostic plots for this
    data.
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