[Date Prev][Date Next][Thread Prev][Thread Next][Date Index][Thread Index]

From |
"Kieran McCaul" <Kieran.McCaul@uwa.edu.au> |

To |
<statalist@hsphsun2.harvard.edu> |

Subject |
RE: st: Survival analysis |

Date |
Wed, 2 Sep 2009 06:08:38 +0800 |

... There isn't anything counterintuitive here: look at the K-M graph. The failures in icp=0 occur in greater number then those in icp=1. They also occur more quickly. In icp=1 the failures take longer to accrue. So overall, icp looks good, but if you start conditioning on some initial period of survival, icp is going to start to look "bad". That's because the flat region in the survival curve for those on icp=0 occurs earlier than it does for those on icp=1. So if you condition on about 2 days of survival, you are in the flat region of icdp=0 (essential no more failures occurring after this), but there are still failure occurring in icp=1. So icp=1 starts to look "bad". It isn't: icp is doing two things. First, it's reducing the risk of failure overall and second, it's delaying failure in those who do ultimately fail. If this were a disease, I would say that without icp people most people survive, but those who don't succumb quickly. It's like cholera: most people survive, but those who die, die quickly. So, people have an ability to fight off the disease. With icp, more people survive and those who eventually fail take longer to fail. So, if this were cholera, icp would be like a treatment that tended to reduce the severity of the cholera symptoms and increased the ability of people to fight off the disease. ______________________________________________ Kieran McCaul MPH PhD WA Centre for Health & Ageing (M573) University of Western Australia Level 6, Ainslie House 48 Murray St Perth 6000 Phone: (08) 9224-2701 Fax: (08) 9224 8009 email: Kieran.McCaul@uwa.edu.au http://myprofile.cos.com/mccaul http://www.researcherid.com/rid/B-8751-2008 ______________________________________________ If you live to be one hundred, you've got it made. Very few people die past that age - George Burns -----Original Message----- From: owner-statalist@hsphsun2.harvard.edu [mailto:owner-statalist@hsphsun2.harvard.edu] On Behalf Of moleps islon Sent: Wednesday, 2 September 2009 2:55 AM To: statalist@hsphsun2.harvard.edu Subject: Re: st: Survival analysis Dear Marten and other listers, Somehow that looks contraintuitive looking at the graphs (and from what i understand I cannot post graphs or links here). But if you look at the following output you`ll see that from patients surviving >.2 ,.5,1 and 4 days the logrank test points in the direction of a beneficial effect first, but detrimental effect afterwards. The PH assumtion is not fulfilled initially, but later. Isn't this suggestive of a breakpoint somewhere around 1 day ?? Regards, M patients surviving >.2 days failure _d: dod analysis time _t: cox Iteration 0: log likelihood = -2393.672 Iteration 1: log likelihood = -2374.6741 Iteration 2: log likelihood = -2374.4875 Iteration 3: log likelihood = -2374.4874 Refining estimates: Iteration 0: log likelihood = -2374.4874 Cox regression -- Breslow method for ties No. of subjects = 971 Number of obs = 971 No. of failures = 357 Time at risk = 248731.5 LR chi2(1) = 38.37 Log likelihood = -2374.4874 Prob > chi2 = 0.0000 ------------------------------------------------------------------------------ _t | Haz. Ratio Std. Err. z P>|z| [95% Conf. Interval] -------------+---------------------------------------------------------------- icp | .4842698 .0598328 -5.87 0.000 .3801186 .616958 ------------------------------------------------------------------------------ Test of proportional-hazards assumption Time: Time ---------------------------------------------------------------- | chi2 df Prob>chi2 ------------+--------------------------------------------------- global test | 25.20 1 0.0000 ---------------------------------------------------------------- failure _d: dod analysis time _t: cox Log-rank test for equality of survivor functions | Events Events icp | observed expected ------+------------------------- 0 | 270 214.69 1 | 87 142.31 ------+------------------------- Total | 357 357.00 chi2(1) = 38.71 Pr>chi2 = 0.0000 patients surviving >.5 days failure _d: dod analysis time _t: cox Iteration 0: log likelihood = -1506.3678 Iteration 1: log likelihood = -1505.0847 Iteration 2: log likelihood = -1505.0842 Refining estimates: Iteration 0: log likelihood = -1505.0842 Cox regression -- Breslow method for ties No. of subjects = 842 Number of obs = 842 No. of failures = 228 Time at risk = 248667 LR chi2(1) = 2.57 Log likelihood = -1505.0842 Prob > chi2 = 0.1091 ------------------------------------------------------------------------------ _t | Haz. Ratio Std. Err. z P>|z| [95% Conf. Interval] -------------+---------------------------------------------------------------- icp | .8043308 .1102187 -1.59 0.112 .614884 1.052146 ------------------------------------------------------------------------------ Test of proportional-hazards assumption Time: Time ---------------------------------------------------------------- | chi2 df Prob>chi2 ------------+--------------------------------------------------- global test | 10.23 1 0.0014 ---------------------------------------------------------------- failure _d: dod analysis time _t: cox Log-rank test for equality of survivor functions | Events Events icp | observed expected ------+------------------------- 0 | 143 131.12 1 | 85 96.88 ------+------------------------- Total | 228 228.00 chi2(1) = 2.64 Pr>chi2 = 0.1044 patients surviving >1 days failure _d: dod analysis time _t: cox Iteration 0: log likelihood = -994.44857 Iteration 1: log likelihood = -992.59906 Iteration 2: log likelihood = -992.59879 Refining estimates: Iteration 0: log likelihood = -992.59879 Cox regression -- Breslow method for ties No. of subjects = 766 Number of obs = 766 No. of failures = 152 Time at risk = 248591 LR chi2(1) = 3.70 Log likelihood = -992.59879 Prob > chi2 = 0.0544 ------------------------------------------------------------------------------ _t | Haz. Ratio Std. Err. z P>|z| [95% Conf. Interval] -------------+---------------------------------------------------------------- icp | 1.366676 .2218148 1.92 0.054 .9942913 1.878528 ------------------------------------------------------------------------------ Test of proportional-hazards assumption Time: Time ---------------------------------------------------------------- | chi2 df Prob>chi2 ------------+--------------------------------------------------- global test | 2.66 1 0.1032 ---------------------------------------------------------------- failure _d: dod analysis time _t: cox Log-rank test for equality of survivor functions | Events Events icp | observed expected ------+------------------------- 0 | 74 85.81 1 | 78 66.19 ------+------------------------- Total | 152 152.00 chi2(1) = 3.79 Pr>chi2 = 0.0516 patients surviving >2 days failure _d: dod analysis time _t: cox Iteration 0: log likelihood = -788.57192 Iteration 1: log likelihood = -783.00942 Iteration 2: log likelihood = -783.00902 Refining estimates: Iteration 0: log likelihood = -783.00902 Cox regression -- Breslow method for ties No. of subjects = 735 Number of obs = 735 No. of failures = 121 Time at risk = 248529 LR chi2(1) = 11.13 Log likelihood = -783.00902 Prob > chi2 = 0.0009 ------------------------------------------------------------------------------ _t | Haz. Ratio Std. Err. z P>|z| [95% Conf. Interval] -------------+---------------------------------------------------------------- icp | 1.840018 .3397673 3.30 0.001 1.28128 2.64241 ------------------------------------------------------------------------------ Test of proportional-hazards assumption Time: Time ---------------------------------------------------------------- | chi2 df Prob>chi2 ------------+--------------------------------------------------- global test | 0.65 1 0.4187 ---------------------------------------------------------------- failure _d: dod analysis time _t: cox Log-rank test for equality of survivor functions | Events Events icp | observed expected ------+------------------------- 0 | 50 68.29 1 | 71 52.71 ------+------------------------- Total | 121 121.00 chi2(1) = 11.33 Pr>chi2 = 0.0008 patients surviving >4 days failure _d: dod analysis time _t: cox Iteration 0: log likelihood = -669.88384 Iteration 1: log likelihood = -661.82737 Iteration 2: log likelihood = -661.82737 Refining estimates: Iteration 0: log likelihood = -661.82737 Cox regression -- Breslow method for ties No. of subjects = 717 Number of obs = 717 No. of failures = 103 Time at risk = 248467 LR chi2(1) = 16.11 Log likelihood = -661.82737 Prob > chi2 = 0.0001 ------------------------------------------------------------------------------ _t | Haz. Ratio Std. Err. z P>|z| [95% Conf. Interval] -------------+---------------------------------------------------------------- icp | 2.229562 .4553754 3.93 0.000 1.494055 3.327152 ------------------------------------------------------------------------------ Test of proportional-hazards assumption Time: Time ---------------------------------------------------------------- | chi2 df Prob>chi2 ------------+--------------------------------------------------- global test | 0.09 1 0.7633 ---------------------------------------------------------------- failure _d: dod analysis time _t: cox Log-rank test for equality of survivor functions | Events Events icp | observed expected ------+------------------------- 0 | 38 58.28 1 | 65 44.72 ------+------------------------- Total | 103 103.00 chi2(1) = 16.37 Pr>chi2 = 0.0001 . end of do-file . On Mon, Aug 31, 2009 at 11:52 AM, Maarten buis<maartenbuis@yahoo.co.uk> wrote: > ----------------------------------------- > Maarten L. Buis > Institut fuer Soziologie > Universitaet Tuebingen > Wilhelmstrasse 36 > 72074 Tuebingen > Germany > > http://www.maartenbuis.nl > ----------------------------------------- > > > --- moleps islon wrote: >> > This is the ouput I´m getting using your approach: >> > >> > n=896, failures=292 >> > >> > stcox var,tvc(var) texp((_t>1)_t) >> > >> > rh >> > >> > var HR 0.64, p=0.005, CI 0.47-0.87 >> > >> > t >> > var HR 1.01,p=0.001,CI 1.01-1.03 >> > >> > So as far as I understand this the interpretation is >> > that the -var- is protective within the first 24hrs, >> > but detrimental afterwards ?? > > --- On Mon, 31/8/09, Maarten buis wrote: >> No, the coefficient in the t equation is an interaction >> effect. So from t =0 to t=1 the hazard ratio increased >> with 1%. So at t=0 the hazard ratio for var is >> 0.64/1.01=0.62. In other words, in the first 24hrs var >> was even more protective than afterwards (but only very >> little, so I doubt whether that has any practical >> relevance). > > Sorry, I did not see that you turned around the inquality > sign (from < to >). So, in your case you assume that the > PH assumption holds in the first 24hrs, and that > afterwards the log hazard ratio changes linearly with time. > So, from t=0 to t=1 the hazard ratio of var is .64, and > after t=1 the hazard ratio increases by 1% every day. At > t=2 the hazard ratio of var is 1.01*.64=.646, at t=3 > 1.01^2*.64=.653, at t=4 1.01^3*.64=.659, etc. > > To get the interpretation I gave in my previous post you > have to replace > stcox var,tvc(var) texp((_t>1)_t) > > with > stcox var,tvc(var) texp((_t<1)_t) > > Hope this helps, > Maarten > > > > > > * > * For searches and help try: > * http://www.stata.com/help.cgi?search > * http://www.stata.com/support/statalist/faq > * http://www.ats.ucla.edu/stat/stata/ > * * For searches and help try: * http://www.stata.com/help.cgi?search * http://www.stata.com/support/statalist/faq * http://www.ats.ucla.edu/stat/stata/ * * For searches and help try: * http://www.stata.com/help.cgi?search * http://www.stata.com/support/statalist/faq * http://www.ats.ucla.edu/stat/stata/

**Follow-Ups**:**Re: st: Survival analysis***From:*moleps islon <moleps2@gmail.com>

**References**:**Re: st: Survival analysis***From:*moleps islon <moleps2@gmail.com>

- Prev by Date:
**Re: st: margins and interactions** - Next by Date:
**Re: st: Graph Box Color** - Previous by thread:
**Re: st: Survival analysis** - Next by thread:
**Re: st: Survival analysis** - Index(es):

© Copyright 1996–2014 StataCorp LP | Terms of use | Privacy | Contact us | What's new | Site index |