MCMCpoissonChange: Markov Chain Monte Carlo for a Poisson Regression Changepoint...

In MCMCpack: Markov Chain Monte Carlo (MCMC) Package

Markov Chain Monte Carlo for a Poisson Regression Changepoint Model

Description

This function generates a sample from the posterior distribution of a Poisson regression model with multiple changepoints. The function uses the Markov chain Monte Carlo method of Chib (1998). The user supplies data and priors, and a sample from the posterior distribution is returned as an mcmc object, which can be subsequently analyzed with functions provided in the coda package.

Usage

MCMCpoissonChange(
  formula,
  data = parent.frame(),
  m = 1,
  b0 = 0,
  B0 = 1,
  a = NULL,
  b = NULL,
  c0 = NA,
  d0 = NA,
  lambda.mu = NA,
  lambda.var = NA,
  burnin = 1000,
  mcmc = 1000,
  thin = 1,
  verbose = 0,
  seed = NA,
  beta.start = NA,
  P.start = NA,
  marginal.likelihood = c("none", "Chib95"),
  ...
)

Arguments

formula	Model formula.
data	Data frame.
m	The number of changepoints.
b0	The prior mean of β. This can either be a scalar or a column vector with dimension equal to the number of betas. If this takes a scalar value, then that value will serve as the prior mean for all of the betas.
B0	The prior precision of β. This can either be a scalar or a square matrix with dimensions equal to the number of betas. If this takes a scalar value, then that value times an identity matrix serves as the prior precision of beta. Default value of 0 is equivalent to an improper uniform prior for beta.
a	a is the shape1 beta prior for transition probabilities. By default, the expected duration is computed and corresponding a and b values are assigned. The expected duration is the sample period divided by the number of states.
b	b is the shape2 beta prior for transition probabilities. By default, the expected duration is computed and corresponding a and b values are assigned. The expected duration is the sample period divided by the number of states.
c0	c_0 is the shape parameter for Gamma prior on λ (the mean). When there is no covariate, this should be provided by users. No default value is provided.
d0	d_0 is the scale parameter for Gamma prior on λ (the mean). When there is no covariate, this should be provided by users. No default value is provided.
lambda.mu	The mean of the Gamma prior on λ. sigma.mu and sigma.var allow users to choose the Gamma prior by choosing its mean and variance.
lambda.var	The variacne of the Gamma prior on λ. sigma.mu and sigma.var allow users to choose the Gamma prior by choosing its mean and variance.
burnin	The number of burn-in iterations for the sampler.
mcmc	The number of MCMC iterations after burn-in.
thin	The thinning interval used in the simulation. The number of MCMC iterations must be divisible by this value.
verbose	A switch which determines whether or not the progress of the sampler is printed to the screen. If verbose is greater than 0, the iteration number and the posterior density samples are printed to the screen every verboseth iteration.
seed	The seed for the random number generator. If NA, current R system seed is used.
beta.start	The starting values for the beta vector. This can either be a scalar or a column vector with dimension equal to the number of betas. The default value of NA will use draws from the Uniform distribution with the same boundary with the data as the starting value. If this is a scalar, that value will serve as the starting value mean for all of the betas. When there is no covariate, the log value of means should be used.
P.start	The starting values for the transition matrix. A user should provide a square matrix with dimension equal to the number of states. By default, draws from the Beta(0.9, 0.1) are used to construct a proper transition matrix for each raw except the last raw.
marginal.likelihood	How should the marginal likelihood be calculated? Options are: none in which case the marginal likelihood will not be calculated, and Chib95 in which case the method of Chib (1995) is used.
...	further arguments to be passed

Details

MCMCpoissonChange simulates from the posterior distribution of a Poisson regression model with multiple changepoints using the methods of Chib (1998) and Fruhwirth-Schnatter and Wagner (2006). The details of the model are discussed in Park (2010).

The model takes the following form:

y_t \sim \mathcal{P}oisson(μ_t)

μ_t = x_t ' β_m,\;\; m = 1, …, M

Where M is the number of states and β_m is paramters when a state is m at t.

We assume Gaussian distribution for prior of β:

β_m \sim \mathcal{N}(b_0,B_0^{-1}),\;\; m = 1, …, M

And:

p_{mm} \sim \mathcal{B}eta(a, b),\;\; m = 1, …, M

Where M is the number of states.

Value

An mcmc object that contains the posterior sample. This object can be summarized by functions provided by the coda package. The object contains an attribute prob.state storage matrix that contains the probability of state_i for each period, and the log-marginal likelihood of the model (logmarglike).

References

Jong Hee Park. 2010. “Structural Change in the U.S. Presidents' Use of Force Abroad.” American Journal of Political Science 54: 766-782. <doi:10.1111/j.1540-5907.2010.00459.x>

Sylvia Fruhwirth-Schnatter and Helga Wagner 2006. “Auxiliary Mixture Sampling for Parameter-driven Models of Time Series of Counts with Applications to State Space Modelling.” Biometrika. 93:827–841.

Siddhartha Chib. 1998. “Estimation and comparison of multiple change-point models.” Journal of Econometrics. 86: 221-241. <doi: 10.1016/S0304-4076(97)00115-2>

Andrew D. Martin, Kevin M. Quinn, and Jong Hee Park. 2011. “MCMCpack: Markov Chain Monte Carlo in R.”, Journal of Statistical Software. 42(9): 1-21. doi: 10.18637/jss.v042.i09.

Siddhartha Chib. 1995. “Marginal Likelihood from the Gibbs Output.” Journal of the American Statistical Association. 90: 1313-1321. <doi: 10.1080/01621459.1995.10476635>

See Also

MCMCbinaryChange, plotState, plotChangepoint

Examples

    ## Not run: 
    set.seed(11119)
    n <- 150
    x1 <- runif(n, 0, 0.5)
    true.beta1 <- c(1,  1)
    true.beta2 <- c(1,  -2)
    true.beta3 <- c(1,  2)

    ## set true two breaks at (50, 100)
    true.s <- rep(1:3, each=n/3)
    mu1 <- exp(1 + x1[true.s==1]*1)
    mu2 <- exp(1 + x1[true.s==2]*-2)
    mu3 <- exp(1 + x1[true.s==3]*2)

    y <- as.ts(c(rpois(n/3, mu1), rpois(n/3, mu2), rpois(n/3, mu3)))
    formula = y ~ x1

    ## fit multiple models with a varying number of breaks
    model0 <-  MCMCpoissonChange(formula, m=0,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")
    model1 <-  MCMCpoissonChange(formula, m=1,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")
    model2 <-  MCMCpoissonChange(formula, m=2,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")
    model3 <-  MCMCpoissonChange(formula, m=3,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")
    model4 <-  MCMCpoissonChange(formula, m=4,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")
    model5 <-  MCMCpoissonChange(formula, m=5,
            mcmc = 1000, burnin = 1000, verbose = 500,
            b0 = rep(0, 2), B0 = 1/5*diag(2), marginal.likelihood = "Chib95")

    ## find the most reasonable one
    print(BayesFactor(model0, model1, model2, model3, model4, model5))

    ## draw plots using the "right" model
    par(mfrow=c(attr(model2, "m") + 1, 1), mai=c(0.4, 0.6, 0.3, 0.05))
    plotState(model2, legend.control = c(1, 0.6))
    plotChangepoint(model2, verbose = TRUE, ylab="Density", start=1, overlay=TRUE)

    ## No covariate case
    model2.1 <- MCMCpoissonChange(y ~ 1, m = 2, c0 = 2, d0 = 1,
             mcmc = 1000, burnin = 1000, verbose = 500,
             marginal.likelihood = "Chib95")
    print(BayesFactor(model2, model2.1))
    
## End(Not run)

MCMCpack documentation built on April 13, 2022, 5:16 p.m.