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===Confidence Bounds===
#REDIRECT [[Recurrent_Event_Data_Analysis#Confidence_Bounds]]
In general, in order to obtain the virtual age, the exact occurrence time of each event (failure) should be available, see equations for Type I and Type 2 models. However, the times are unknown until the corresponding events occur. For this reason, there are no closed-form expressions for total failure number and failure intensity, which are functions of failure times and virtual age. Therefore, in Weibull++, Monte Carlo simulation is used to predict values of virtual time, failure number, MTBF and failure rate. The approximate confidence bounds obtained from simulation are provided. The uncertainty of model parameters is also considered in the bounds.
 
====Bounds on Cumulative Failure (Event) Numbers====
The variance of the cumulative failure number  <math>N(t)</math>  is:
 
::<math>Var[N(t)]=Var\left[ E(N(t)|\lambda ,\beta ,q) \right]+E\left[ Var(N(t)|\lambda ,\beta ,q) \right]</math>
 
The first term accounts for the uncertainty of the parameter estimation. The second term considers the uncertainty caused by the renewal process even when model parameters are fixed. However, unless  <math>q=1</math> ,  <math>Var\left[ E(N(t)|\lambda ,\beta ,q) \right]</math>  cannot be calculated because  <math>E(N(t))</math>  cannot be expressed as a closed-form function of  <math>\lambda ,\beta ,</math>  and  <math>q</math> . In order to consider the uncertainty of the parameter estimation,  <math>Var\left[ E(N(t)|\lambda ,\beta ,q) \right]</math>  is approximated by:
 
::<math>Var\left[ E(N(t)|\lambda ,\beta ,q) \right]=Var[E(N({{v}_{t}})|\lambda ,\beta )]=Var[\lambda v_{t}^{\beta }]</math>
 
where  <math>{{v}_{t}}</math>  is the expected virtual age at time  <math>t</math>  and  <math>Var[\lambda v_{t}^{\beta }]</math>  is::
 
::<math>\begin{align}
  & Var[\lambda v_{t}^{\beta }]= & {{\left( \frac{\partial (\lambda v_{t}^{\beta })}{\partial \beta } \right)}^{2}}Var(\hat{\beta })+{{\left( \frac{\partial (\lambda v_{t}^{\beta })}{\partial \lambda } \right)}^{2}}Var(\hat{\lambda }) \\
&  +2\frac{\partial (\lambda v_{t}^{\beta })}{\partial \beta }\frac{\partial (\lambda v_{t}^{\beta })}{\partial \lambda }Cov(\hat{\beta },\hat{\lambda }) 
\end{align}</math>
 
By conducting this approximation, the uncertainty of  <math>\lambda </math>  and  <math>\beta </math>  are considered. The value of  <math>{{v}_{t}}</math>  and the value of the second term in the equation for the variance of number of failures are obtained through the Monte Carlo simulation using parameters  <math>\hat{\lambda },\hat{\beta },\hat{q},</math>  which are the ML estimators. The same simulation is used to estimate the cumulative number of failures  <math>\hat{N}(t)=E(N(t)|\hat{\lambda },\hat{\beta },\hat{q})</math>  .
 
Once the variance and the expected value of  <math>N(t)</math>  have been obtained, the bounds can be calculated by assuming  <math>N(t)</math>  is lognormally distributed as:
 
::<math>\frac{\ln N(t)-\ln \hat{N}(t)}{\sqrt{Var(\ln N(t))}}\tilde{\ }N(0,1)</math>
 
The upper and lower bounds for a given confidence level  <math>\alpha </math>  can be calculated by:
 
::<math>N{{(t)}_{U,L}}=\hat{N}(t){{e}^{\pm {{z}_{a}}\sqrt{Var(N(t))}/\hat{N}(t)}}</math>
 
where  <math>{{z}_{a}}</math>  is the standard normal distribution.
 
If  <math>N(t)</math>  is assumed to be normally distributed, the bounds can be calculated by:
 
::<math>N{{(t)}_{U}}=\hat{N}(t)+{{z}_{a}}\sqrt{Var(N(t))}</math>
 
::<math>N{{(t)}_{L}}=\hat{N}(t)-{{z}_{a}}\sqrt{Var(N(t))}</math>
 
In Weibull++, the  <math>N{{(t)}_{U}}</math>  is the smaller of the upper bounds obtained from lognormal and normal distribution appoximation. The  <math>N{{(t)}_{L}}</math>  is set to the largest of the lower bounds obtained from lognormal and normal distribution appoximation. This combined method can prevent the out-of-range values of bounds for some small  <math>t</math>  values.
Bounds of Cumulative Failure Intensity and MTBF
For a given time  <math>t</math> , the expected value of cumulative MTBF  <math>{{m}_{c}}(t)</math>  and cumulative failure intensity  <math>{{\lambda }_{c}}(t)</math>  can be calculated using the following equations:
 
::<math>{{\hat{\lambda }}_{c}}(t)=\frac{\hat{N}(t)}{t};{{\hat{m}}_{c}}(t)=\frac{t}{\hat{N}(t)}</math>
 
The bounds can be easily obtained from the corresponding bounds of  <math>N(t).</math>
 
::<math>\begin{align}
  & {{{\hat{\lambda }}}_{c}}{{(t)}_{L}}= & \frac{\hat{N}{{(t)}_{L}}}{t};\text{  }{{{\hat{\lambda }}}_{c}}{{(t)}_{L}}=\frac{\hat{N}{{(t)}_{L}}}{t};\text{  } \\
& {{{\hat{m}}}_{c}}{{(t)}_{L}}= & \frac{t}{\hat{N}{{(t)}_{U}}};\text{  }{{{\hat{m}}}_{c}}{{(t)}_{U}}=\frac{t}{\hat{N}{{(t)}_{L}}} 
\end{align}</math>
 
====Bounds on Instantaneous Failure Intensity and MTBF====
The instantaneous failure intensity is given by:
 
::<math>{{\lambda }_{i}}(t)=\lambda \beta v_{t}^{\beta -1}</math>
 
where  <math>{{v}_{t}}</math>  is the virtual age at time  <math>t.</math>  When  <math>q\ne 1,</math>  it is obtained from simulation. When  <math>q=1</math> ,  <math>{{v}_{t}}=t</math>  from model Type I and Type 2.
 
The variance of instantaneous failure intensity can be calculated by:
 
::<math>\begin{align}
  & Var({{\lambda }_{i}}(t))= {{\left( \frac{\partial {{\lambda }_{i}}(t)}{\partial \beta } \right)}^{2}}Var(\hat{\beta })+{{\left( \frac{\partial {{\lambda }_{i}}(t)}{\partial \lambda } \right)}^{2}}Var(\hat{\lambda }) \\
&  +2\frac{\partial {{\lambda }_{i}}(t)}{\partial \beta }\frac{\partial {{\lambda }_{i}}(t)}{\partial \lambda }Cov(\hat{\beta },\hat{\lambda })+{{\left( \frac{\partial {{\lambda }_{i}}(t)}{\partial v(t)} \right)}^{2}}Var({{{\hat{v}}}_{t}}) 
\end{align}</math>
 
The expected value and variance of  <math>{{v}_{t}}</math>  are obtained from the Monte Carlo simulation with parameters  <math>\hat{\lambda },\hat{\beta },\hat{q}.</math>  Because of the simulation accuracy and the convergence problem in calculation of  <math>Var(\hat{\beta }),Var(\hat{\lambda })</math>  and  <math>Cov(\hat{\beta },\hat{\lambda }),</math>  <math>Var({{\lambda }_{i}}(t))</math>  can be a negative value at some time points. When this case happens, the bounds of instantaneous failure intensity are not provided.
 
Once the variance and the expected value of  <math>{{\lambda }_{i}}(t)</math>  are obtained, the bounds have been calculated by assuming  <math>{{\lambda }_{i}}(t)</math>  is lognormally distributed as:
 
::<math>\frac{\ln {{\lambda }_{i}}(t)-\ln {{{\hat{\lambda }}}_{i}}(t)}{\sqrt{Var(\ln {{\lambda }_{i}}(t))}}\tilde{\ }N(0,1)</math>
 
The upper and lower bounds for a given confidence level  <math>\alpha </math>  can be calculated by:
 
::<math>{{\lambda }_{i}}(t)={{\hat{\lambda }}_{i}}(t){{e}^{\pm {{z}_{a}}\sqrt{Var({{\lambda }_{i}}(t))}/{{{\hat{\lambda }}}_{i}}(t)}}</math>
 
where  <math>{{z}_{a}}</math>  is the standard normal distribution.
 
If  <math>{{\lambda }_{i}}(t)</math>  is assumed to be normally distributed, the bounds can be calculated by:
 
::<math>{{\lambda }_{i}}{{(t)}_{U}}={{\hat{\lambda }}_{i}}(t)+{{z}_{a}}\sqrt{Var(N(t))}</math>
 
::<math>{{\lambda }_{i}}{{(t)}_{L}}={{\hat{\lambda }}_{i}}(t)-{{z}_{a}}\sqrt{Var(N(t))}</math>
 
In Weibull++,  <math>{{\lambda }_{i}}{{(t)}_{U}}</math>  is set to the smaller of the two upper bounds obtained from the above lognormal and normal distribution appoximation.  <math>{{\lambda }_{i}}{{(t)}_{L}}</math>  is set to the largest of the two lower bounds obtained from the above lognormal and normal distribution appoximation. This combination method can prevent the out of range values of bounds when  <math>t</math>  values are small.
 
For a given time  <math>t</math> , the expected value of cumulative MTBF  <math>{{m}_{i}}(t)</math>  is:
 
::<math>{{\hat{m}}_{i}}(t)=\frac{1}{{{{\hat{\lambda }}}_{i}}(t)}\text{  }</math>
 
The upper and lower bounds can be easily obtained from the corresponding bounds of  <math>{{\lambda }_{i}}(t):</math> 
 
::<math>{{\hat{m}}_{i}}{{(t)}_{U}}=\frac{1}{{{{\hat{\lambda }}}_{i}}{{(t)}_{L}}}</math>
 
 
::<math>{{\hat{m}}_{i}}{{(t)}_{L}}=\frac{1}{{{{\hat{\lambda }}}_{i}}{{(t)}_{U}}}</math>
 
====Bounds on Conditional Reliability====
Given mission start time  <math>{{t}_{0}}</math>  and mission time  <math>T</math> , the conditional reliability can be calculated by:
 
::<math>R(T|{{t}_{0}})=\frac{R(T+{{v}_{0}})}{R({{v}_{0}})}={{e}^{-\lambda [{{({{v}_{0}}+T)}^{\beta }}-{{v}_{0}}]}}</math>
 
<math>{{v}_{0}}</math>  is the virtual age corresponding to time  <math>{{t}_{0}}</math> . The expected value and the variance of  <math>{{v}_{0}}</math>  are obtained from Monte Carlo simulation. The variance of the conditional reliability  <math>R(T|{{t}_{0}})</math>  is:
 
::<math>\begin{align}
  & Var(R)=  {{\left( \frac{\partial R}{\partial \beta } \right)}^{2}}Var(\hat{\beta })+{{\left( \frac{\partial R}{\partial \lambda } \right)}^{2}}Var(\hat{\lambda }) \\
&  +2\frac{\partial R}{\partial \beta }\frac{\partial R}{\partial \lambda }Cov(\hat{\beta },\hat{\lambda })+{{\left( \frac{\partial R}{\partial {{v}_{0}}} \right)}^{2}}Var({{{\hat{v}}}_{0}}) 
\end{align}</math>
 
Because of the simulation accuracy and the convergence problem in calculation of  <math>Var(\hat{\beta }),Var(\hat{\lambda })</math>  and  <math>Cov(\hat{\beta },\hat{\lambda }),</math>  <math>Var(R)</math>  can be a negative value at some time points. When this case happens, the bounds are not provided.
 
The bounds are based on:
 
::<math>\log \text{it}(\hat{R}(T))\tilde{\ }N(0,1)</math>
 
::<math>\log \text{it}(\hat{R}(T))=\ln \left\{ \frac{\hat{R}(T)}{1-\hat{R}(T)} \right\}</math>
 
The confidence bounds on reliability are given by:
 
::<math>R=\frac{{\hat{R}}}{\hat{R}+(1-\hat{R}){{e}^{\pm \sqrt{Var(R)}/[\hat{R}(1-\hat{R})]}}}</math>
 
It will be compared with the bounds obtained from:
 
::<math>R=\hat{R}{{e}^{\pm {{z}_{a}}\sqrt{Var(R)}/\hat{R}}}</math>
 
The smaller of the two upper bounds will be the final upper bound and the larger of the two lower bounds will be the final lower bound.
 
 
'''Example 4:'''
{{Example: Recurrent Events Data Parameteric Air-Condition Example}}

Latest revision as of 22:10, 20 August 2012

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