multivariate poisson hidden markov models for analysis of spatial ...

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PERMISSION TO USE The author has agreed that the libraries of this University may provide the thesis freely available for inspection. Moreover, the author has agreed that permission for copying of the thesis in any manner, entirely or in part, for scholarly purposes may be granted by the Professor or Professors who supervised my thesis work or in their absence, by the Head of the Department of Mathematics and Statistics or the Dean of the College in which the thesis work was done. It is understood that any copying or publication or use of the thesis or parts thereof for finanancial gain shall not be allowed without my written permission. It is also understood that due recognition shall be given to the author and to the University of Saskatchewan in any scholarly use which may be made of any material in this thesis. Requests for permission to copy or to make other use of any material in the thesis should be addressed to: Head Department of Mathematics and Statistics University of Saskatchewan 106, Wiggins Road Saskatoon, Saskatchewan Canada, S7N 5E6 i
ABSTRACT Multivariate count data are found in a variety of fields. For modeling such data, one may consider the multivariate Poisson distribution. Overdispersion is a problem when modeling the data with the multivariate Poisson distribution. Therefore, in this thesis we propose a new multivariate Poisson hidden Markov model based on the extension of independent multivariate Poisson finite mixture models, as a solution to this problem. This model, which can take into account the spatial nature of weed counts, is applied to weed species counts in an agricultural field. The distribution of counts depends on the underlying sequence of states, which are unobserved or hidden. These hidden states represent the regions where weed counts are relatively homogeneous. Analysis of these data involves the estimation of the number of hidden states, Poisson means and covariances. Parameter estimation is done using a modified EM algorithm for maximum likelihood estimation. We extend the univariate Markov-dependent Poisson finite mixture model to the multivariate Poisson case (bivariate and trivariate) to model counts of two or three species. Also, we contribute to the hidden Markov model research area by developing Splus/R codes for the analysis of the multivariate Poisson hidden Markov model. Splus/R codes are written for the estimation of multivariate Poisson hidden Markov model using the EM algorithm and the forward-backward procedure and the bootstrap estimation of standard errors. The estimated parameters are used to calculate the goodness of fit measures of the models. ii
Page 1: MULTIVARIATE POISSON HIDDEN MARKOV
Page 5 and 6: ACKNOWLEDGEMENT First I would like
Page 7 and 8: TABLE OF CONTENTS PERMISSION TO USE
Page 9 and 10: 6.4 Data analysis..................
Page 11 and 12: Table 7.7: Loglikelihood and AIC to
Page 13 and 14: Figure 6.10: Loglikelihood, AIC and
Page 15 and 16: CHAPTER 1 GENERAL INTRODUCTION 1.1
Page 17 and 18: North Carolina, is modelled by Symo
Page 19 and 20: concept of Markov models to include
Page 21 and 22: egularity constraints on the underl
Page 23 and 24: CHAPTER 2 HIDDEN MARKOV MODELS ( HM
Page 25 and 26: Given the coin tossing experiment,
Page 27 and 28: P 11 P 22 P 12 1 2 P 21 P 32 P 13 P
Page 29 and 30: 0.8 0.6 0.2 1 0.4 2 (1) P [H]=2/3 (
Page 31 and 32: … Urn 1 Urn 2 Urn N P[Red]= b 1 (
Page 33 and 34: 5. The probability distribution of
Page 35 and 36: focus of this section. Random field
Page 37 and 38: Now consider a random field { X ( s
Page 39 and 40: for some real β . Again, the denom
Page 41 and 42: Since original HMMs were designed a
Page 43 and 44: CHAPTER 3 INFERENCE IN HIDDEN MARKO
Page 45 and 46: sequence. If we have several compet
Page 47 and 48: Using this equation we can calculat
Page 49 and 50: 3.2.2 Problem 2 and its solution Gi
Page 51 and 52: Letting Ut( S1 = i1, S2 = i2,..., S
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ξ α () iPβ ( jb ) ( y ) t ij t+
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ˆ ( n) = b j Expected Number of ti
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CHAPTER 4 HIDDEN MARKOV MODEL AND T
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4.2.1 Wild Oats Figure 4.1: Wild Oa
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4.2.2.1 Effects on crop quality Wil
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at each of the 150 grid locations (
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In the literature review (section 1
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estimated through the observations
Page 69 and 70:
CHAPTER 5 MULTIVARIATE POISSON DIST
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Y Y Y 1 2 3 = X = X 1 = X 2 3 + X +
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educe the computational burden; how
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and y 3 as illustrated above. Again
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q In general, the number of paramet
Page 79 and 80:
Similar to the fully structured mod
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ecause the former captures more of
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(Tsiamyrtzis and Karlis, 2004). The
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notation, the following recursive s
Page 87 and 88:
5.2.2 The multivariate Poisson dist
Page 89 and 90:
ypy ( ,0,0) = θ py ( − 1,0,0) y1
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ecurrence relationship ypy 1 ( 1 ,
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Raftery, 1998); identification of t
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maximization (EM) algorithm is appl
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the EM algorithms for use on very l
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Another alternative is to use the p
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5.3.5 Estimation for the multivaria
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j j E[ X 12 i | Yi , Z ij = 1, Φ ]
Page 105 and 106:
5.4 Multivariate Poisson hidden Mar
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where P = Pr( S = k | S − 1 j), 1
Page 109 and 110:
P jk n ∑ vˆ jk i= 2 = n m ∑∑
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E[ X | Y, u ( i) = 1, Φ ] = d = y
Page 113 and 114:
The bootstrap method is a powerful
Page 115 and 116:
eplications are generally sufficien
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Y and assumes a probability distrib
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For the case of two categorical var
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ejected. In this situation, the (sm
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the Poisson distribution is well su
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0 1 2 3 4 Wild Buckwheat species109
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Table 6.4: The frequency of occurre
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6.4.1 Results for the different mul
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Proportion 1.0 0.9 0.8 0.7 0.6 0.5
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-600 -650 -700 Loglikelihood -750 -
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Figure 6.7 illustrates the evolutio
Page 137 and 138:
Table 6.8: Parameter estimates (boo
Page 139 and 140:
common covariance and the four stat
Page 141 and 142:
-600 -700 -800 Loglikelihood -900 -
Page 143 and 144:
Table 6.11: Parameter estimates (bo
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6.5 Comparison of the different mod
Page 147 and 148:
loglikelihood providing at least a
Page 149 and 150:
illustrates the contour plot of the
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(a) Independent Contour 1 Contour 2
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Karlis and Meligkotsidou (2006) dis
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The mean vector and the covariance
Page 157 and 158:
The simple moments of B are polynom
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and E ( Y ) = AM where ⎡λ1 ⎤
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7.5 Applications In addition to wee
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The estimated covariance matrix and
Page 165 and 166:
The estimated covariance matrix (AI
Page 167 and 168:
Table 7.6 Bacterial counts by 3 sam
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Table 7.8: Loglikelihood and AIC to
Page 171 and 172:
(c) Finite mixture with the five co
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(i) Hidden Markov model with the fi
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CHAPTER 8 COMPUTATIONAL EFFICIENCY
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less time compared to the multivari
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1400 1200 CPU time (1/100 second) 1
Page 181 and 182:
1400 1200 CPU time (1/100 second) 1
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In this thesis, three species count
Page 185 and 186:
In the applications of the HMMs, li
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indication of the relative goodness
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underlying data. The advantage of t
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9.6 Further research We can present
Page 193 and 194:
REFERENCES 1. Aas, K., Eikvil, L. a
Page 195 and 196:
17. Bicego, M., Murino, V. & Figuei
Page 197 and 198:
33. Descombes, X., Morris, R.D., Ze
Page 199 and 200:
Department of Statistics, Universit
Page 201 and 202:
66. Li C.S., Lu J.C., Park J., Kim
Page 203 and 204:
85. Petrie T. (1969). Probabilistic
Page 205 and 206:
104. University of Manitoba, Depart
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z0
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threep2[i]
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loglike[nit]
Page 213 and 214:
theta33
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} prob[g1+1, g2 + 1]
Page 217 and 218:
theta131
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threep22[i]
Page 221 and 222:
dens=matrix(0,nrow=T,ncol=N) alpha=
Page 223 and 224:
# vˆ jk ( i) = P jk f ( y ; λ i
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