p-spline mixed models for spatio-temporal...
TRANSCRIPT
P-spline mixed models for spatio-temporal data
María Durbánjoint work with Dae-Jin Lee
DEPARTMENT OF STATISTICSUNIVERSIDAD CARLOS III DE MADRID
June 2009
Uc3m/ Dept. of Statistics 1First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Outline
1 P-splinesMixed models approachMultidimensional P-splines
2 P-splines for spatial count dataSpatial smoothingSmooth-CAR modelApplication: Scottish Lip Cancer data
3 Spatio-temporal data Smoothing with P-splinesANOVA-Type Interaction ModelsApplication Environmental spatio-temporal data
4 Spatio-temporal Disease Mapping
Uc3m/ Dept. of Statistics 2First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Outline
1 P-splinesMixed models approachMultidimensional P-splines
2 P-splines for spatial count dataSpatial smoothingSmooth-CAR modelApplication: Scottish Lip Cancer data
3 Spatio-temporal data Smoothing with P-splinesANOVA-Type Interaction ModelsApplication Environmental spatio-temporal data
4 Spatio-temporal Disease Mapping
Uc3m/ Dept. of Statistics 3First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I Penalized Likelihood splines (Eilers & Marx, 1996):
• Given the data (xi,yi), i = 1, ...,n
• Fit a sum of local basis functions:
yi = f (xi) + εi, ε ∼ N (0,σ2)
where f (xi) = Bθ and
I B = B(x) is a Regression Basis, and
I θ is a vector of coefficients.
• Control the fit through a smoothing parameter (λ).
» Regression Basis
Uc3m/ Dept. of Statistics 4First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I B-splines Basis:
• p + 1 Piece-wise polynomialsof degree p.
• Connected by knots.• In general the choice is p=3,
cubic spline.
B-splines of degree p:
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Uc3m/ Dept. of Statistics 5First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I B-splines Basis:
• y = f (xi) = Bθ
• B-splines Regression:
min S(θ; y) = ‖y− Bθ‖2
θ = (B′B)−1B′y
I Optimal selection ofknots (Complex).
• P-Splines: add a penalty tocontrol smoothness.
Example:
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» Methodology
Uc3m/ Dept. of Statistics 6First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I B-splines Basis:
• y = f (xi) = Bθ
• B-splines Regression:
min S(θ; y) = ‖y− Bθ‖2
θ = (B′B)−1B′y
I Optimal selection ofknots (Complex).
• P-Splines: add a penalty tocontrol smoothness.
Example:
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» Methodology
Uc3m/ Dept. of Statistics 6First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I B-splines Basis:
• y = f (xi) = Bθ
• B-splines Regression:
min S(θ; y) = ‖y− Bθ‖2
θ = (B′B)−1B′y
I Optimal selection ofknots (Complex).
• P-Splines: add a penalty tocontrol smoothness.
Example:
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» Methodology
Uc3m/ Dept. of Statistics 6First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
Methodology:
• Minimize the penalized sum of squares (PSS):
S(θ; y, λ)p = ‖y− Bθ‖2 + PENALTY
• The PENALTY term, controls the smoothness of the fit by λ.
I Eilers & Marx (1996):⇒ (discrete) Penalty over adjacent coefficients θ.
I Lang & Brezger (2004):⇒ “Bayesian P-splines”: random walk priors for θ, e.g.:
θ|θm−1 ∼ N (θm−1, τ2), or
θ|θm−1,θm−2 ∼ N (2θm−1 − θm−2, τ2)
Uc3m/ Dept. of Statistics 7First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
Methodology:
• Minimize the penalized sum of squares (PSS):
S(θ; y, λ)p = ‖y− Bθ‖2 + PENALTY
• The PENALTY term, controls the smoothness of the fit by λ.
I Eilers & Marx (1996):⇒ (discrete) Penalty over adjacent coefficients θ.
I Lang & Brezger (2004):⇒ “Bayesian P-splines”: random walk priors for θ, e.g.:
θ|θm−1 ∼ N (θm−1, τ2), or
θ|θm−1,θm−2 ∼ N (2θm−1 − θm−2, τ2)
Uc3m/ Dept. of Statistics 7First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
Methodology:
• Minimize the penalized sum of squares (PSS):
S(θ; y, λ)p = ‖y− Bθ‖2 + PENALTY
• The PENALTY term, controls the smoothness of the fit by λ.
I Eilers & Marx (1996):⇒ (discrete) Penalty over adjacent coefficients θ.
I Lang & Brezger (2004):⇒ “Bayesian P-splines”: random walk priors for θ, e.g.:
θ|θm−1 ∼ N (θm−1, τ2), or
θ|θm−1,θm−2 ∼ N (2θm−1 − θm−2, τ2)
Uc3m/ Dept. of Statistics 7First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
• PSS becomes:S(θ; y, λ)p = ‖y− Bθ‖2 + θ′Pθ
I P = λD′D.I λ is the smoothing parameter.I D are difference matrices.
• For given λ , min S(θ; y, λ)p
θ =(B′B + λD′D
)−1 B′y
I λ can be selected by CV, GCV, AIC or BIC.
Uc3m/ Dept. of Statistics 8First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
• PSS becomes:S(θ; y, λ)p = ‖y− Bθ‖2 + θ′Pθ
I P = λD′D.I λ is the smoothing parameter.I D are difference matrices.
• For given λ , min S(θ; y, λ)p
θ =(B′B + λD′D
)−1 B′y
I λ can be selected by CV, GCV, AIC or BIC.
Uc3m/ Dept. of Statistics 8First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
• PSS becomes:S(θ; y, λ)p = ‖y− Bθ‖2 + θ′Pθ
I P = λD′D.I λ is the smoothing parameter.I D are difference matrices.
• For given λ , min S(θ; y, λ)p
θ =(B′B + λD′D
)−1 B′y
I λ can be selected by CV, GCV, AIC or BIC.
Uc3m/ Dept. of Statistics 8First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I 1d P-splines:
• No penalty over coefficients.
• Penalty over coefficients.
Example:
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B-splines basis and θ without penalty
» Advantages
Uc3m/ Dept. of Statistics 9First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
I 1d P-splines:
• No penalty over coefficients.
• Penalty over coefficients.
Example:
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0.0 0.2 0.4 0.6 0.8 1.0
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24
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B-splines basis and θ with penalty
» Advantages
Uc3m/ Dept. of Statistics 9First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines“The Flexible Smoother”
Advantages over other smoothers:• Low-Rank : “dim(B) < dim(data)”.
• Computationally efficient: “# knots ≤ 40”.
• Selection of number and Location of knots is NOT and issue.
• Discrete Penalties over the θ, not over the fitted curve.
• Easy extension to:I Mixed models,I non-gaussian data (GLM’s) andI Multidimensional smoothing.I Spatial and Spatio-temporal smoothing.
» Mixed models
Uc3m/ Dept. of Statistics 10First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
I Reformulate:
• Model y = Bθ + ε, into
y = Xβ + Zα + ε, ε ∼ N (0,σ2I)
I where X and Z are “fixed” and “random” effects matrices.
I with coefficients β and α ∼ N (0,G), and G = σ2αR
I λ = σ2
σ2α
» Reparameterization
Uc3m/ Dept. of Statistics 11First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
I Reformulate:
• Model y = Bθ + ε, into
y = Xβ + Zα + ε, ε ∼ N (0,σ2I)
I where X and Z are “fixed” and “random” effects matrices.
I with coefficients β and α ∼ N (0,G), and G = σ2αR
I λ = σ2
σ2α
» Reparameterization
Uc3m/ Dept. of Statistics 11First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
I Reparameterization:
B ≡ [ X : Z ]⇒ Bθ = Xβ + Zα
IWe use the Singular Value Decomposition (SVD) on D′D
» SVD
Uc3m/ Dept. of Statistics 12First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
I Singular Value Decomposition (SVD)
D′D = UΣU′
• with U = [Un : Us]
D′D = [Un : Us]
[0d
Σ
] [ U′nU′s
]
I Σ ≡ non-null eigenvalues.I Un ≡ eigenvectors corresponding to the null eigenvalues.I Us ≡ eigenvectors corresponding to the non-null eigenvalues.
Uc3m/ Dept. of Statistics 13First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
• The fix effects (β) are unpenalized and
• The Penalty θ′Pθ becomesα′Fα
where F = λΣ is diagonal.
• And the random effects (α) covariance matrix G:
G = σ2F−1
• Mixed Model Basis:
X = [ 1 : x ]
Z = BUs
Uc3m/ Dept. of Statistics 14First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splinesA mixed model approach
Advantages:
• Flexibility:
I Easy incorporation of smoothing in complex models (“spatial” randomeffects and/or correlated errors).
• Mixed Models Theory:
I Estimation and Inference.
• Software Implementation.
I R, Splus, MATLAB or SAS.
• Extension to non-gaussian data:
I Generalized Linear Mixed Models (GLMM)
Uc3m/ Dept. of Statistics 15First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
Example: 2d-array
• Data Y = yij, i = 1, ..., n1 and j = 1, ..., n2
• Array structure: n1 rows and n2columns
Y =
y11 y12 · · · y1n2y21 y22 · · · y2n2...
.... . .
...yn11 · · · · · · yn1n2
• Regressors:
x1 = (x11, · · · , x1n1 )′
x2 = (x21, · · · , x2n2 )′
x.1
x.2
(a) Simulated data
Uc3m/ Dept. of Statistics 16First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
I Use of Tensor Products of B-splines (Durbán et al, 2002):
Example: 2d-array
• Marginal Basis:
• B1 = B1(x1), of dim. n1 × c1.• B2 = B2(x2), of dim. n2 × c2.
• 2d B-splines Basis:
• Kronecker Product (⊗) ofmarginal basis:
B = B2⊗B1, of dim. n1n2×c1c2x2
x1
2d
−B
sp
line
x2x1
2d
−B
sp
line
Uc3m/ Dept. of Statistics 17First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
I Use of Tensor Products of B-splines (Durbán et al, 2002):
Example: 2d-array
• Marginal Basis:
• B1 = B1(x1), of dim. n1 × c1.• B2 = B2(x2), of dim. n2 × c2.
• 2d B-splines Basis:
• Kronecker Product (⊗) ofmarginal basis:
B = B2⊗B1, of dim. n1n2×c1c2x2
x1
2d
−B
sp
line
x2x1
2d
−B
sp
line
Uc3m/ Dept. of Statistics 17First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
Model:
y = f (x1, x2) + ε,
with yn1n2×1
• In matrix form, y = Bθ can be written as:
Y = B1AB2, of dim n1 × n2
where A is a matrix c1 × c2 of coefficients θ of length c1c2 × 1.
IDEA:
• Set penalties over Θ.
• Row-wise Penalty: θ′(Ic2 ⊗D′1D1
)θ
• Column-wise Penalty: θ′(D′2D2 ⊗ Ic1
)θ
Uc3m/ Dept. of Statistics 18First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
Model:
y = f (x1, x2) + ε,
with yn1n2×1
• In matrix form, y = Bθ can be written as:
Y = B1AB2, of dim n1 × n2
where A is a matrix c1 × c2 of coefficients θ of length c1c2 × 1.
IDEA:
• Set penalties over Θ.
• Row-wise Penalty: θ′(Ic2 ⊗D′1D1
)θ
• Column-wise Penalty: θ′(D′2D2 ⊗ Ic1
)θ
Uc3m/ Dept. of Statistics 18First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
I Penalty Matrix in 2d:
P = λ1 Ic2 ⊗D′1D1︸ ︷︷ ︸P1
+λ2 D′2D2 ⊗ Ic1︸ ︷︷ ︸P2
• λ1 and λ2 are the smoothing parameters in each dimension.
• Anisotropy: (λ1 6= λ2)
Uc3m/ Dept. of Statistics 19First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splinesMixed Models Representation
I As in 1d Case:
Example:
I The Mixed Model consists of:
y = Xβ + Zα(Linear/Fixed) (Non-Linear/Random)
x.1
x.2
(b) Fitted Surface
x.1
x.2
(a) Linear/Fixed part
x.1
x.2
(b) Non−linear/Random part
Uc3m/ Dept. of Statistics 20First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
I Mixed Models Representation:
• As in 1d case, the aim is:
B ≡ [ X : Z ] =⇒ Bθ = Xβ + Zα
• The SVD over P allows the simultaneous diagonalization of D′1D1 and D′2D2
• The penalty P becomes F (block diagonal matrix):
F =
λ2Σ2 ⊗ I2
λ1I2 ⊗ Σ1
λ1Ic2−2 ⊗ Σ1 + λ2Σ2 ⊗ Ic1−2
» Model
Uc3m/ Dept. of Statistics 21First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
ANOVA-type Decomposition of Smooth Surfaces:
y = f (x1) + f (x2) + f (x1, x2)(additive term for x1 ) (additive term for x2) (interaction term for x1, x2)
X1
X2
Y
Fitted Surface
X1
X2
Y
Additive term for x1
X1X2
Y
Additive term for x2
X1
X2
Y
Non−additive term
» Advantages
Uc3m/ Dept. of Statistics 22First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Multidimensional P-splines
Advantages:
• Extension to d-dimensions:
B = B2 ⊗ B1 ⊗ · · · ⊗ Bd
• Efficient algorithms:
• Currie et al (2006): Generalized Linear Array Models (GLAM)
• Anisotropy (different smoothing for each dimension):
• Complex models: spatial data smoothing
Uc3m/ Dept. of Statistics 23First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Outline
1 P-splinesMixed models approachMultidimensional P-splines
2 P-splines for spatial count dataSpatial smoothingSmooth-CAR modelApplication: Scottish Lip Cancer data
3 Spatio-temporal data Smoothing with P-splinesANOVA-Type Interaction ModelsApplication Environmental spatio-temporal data
4 Spatio-temporal Disease Mapping
Uc3m/ Dept. of Statistics 24First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataP-splines for spatial smoothing
IWe propose:
• 2d P-splines:
• Geostatistics: at sampling locations.
• Regional/areal: at the centroids.
I Models of the form:y = f (lon, lat) + ε
where
• f (lon, lat) is a large-scale spatial smooth trend: Xβ + Zα.
• The mixed model allows the simultaneous estimation of smoothing andspatial correlation.
» Spatial count data
Uc3m/ Dept. of Statistics 25First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataP-splines for spatial smoothing
IWe propose:
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● • 2d P-splines:
• Geostatistics: at sampling locations.
• Regional/areal: at the centroids.
I Models of the form:y = f (lon, lat) + ε
where
• f (lon, lat) is a large-scale spatial smooth trend: Xβ + Zα.
• The mixed model allows the simultaneous estimation of smoothing andspatial correlation.
» Spatial count data
Uc3m/ Dept. of Statistics 25First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataP-splines for spatial smoothing
IWe propose:
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• 2d P-splines:
• Geostatistics: at sampling locations.
• Regional/areal: at the centroids.
I Models of the form:y = f (lon, lat) + ε
where
• f (lon, lat) is a large-scale spatial smooth trend: Xβ + Zα.
• The mixed model allows the simultaneous estimation of smoothing andspatial correlation.
» Spatial count data
Uc3m/ Dept. of Statistics 25First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataP-splines for spatial smoothing
IWe propose:
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• 2d P-splines:
• Geostatistics: at sampling locations.
• Regional/areal: at the centroids.
I Models of the form:y = f (lon, lat) + ε
where
• f (lon, lat) is a large-scale spatial smooth trend: Xβ + Zα.
• The mixed model allows the simultaneous estimation of smoothing andspatial correlation.
» Spatial count data
Uc3m/ Dept. of Statistics 25First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataBasis for Spatial Data
I B-spline Basis for spatial data:
• Given that data are NOT in an array
B = B2 ⊗ B1 replace by B2�B1
� denotes the “Row-wise Kronecker” or Box-Product.
Def. Box-Product:
B2�B1 = (B2 ⊗ 1c1)� (1c2 ⊗ B1)
� is the “element-wise” product.
Uc3m/ Dept. of Statistics 26First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataI In many applications:
• Collect count data observed in regions or areas.• E.g.: # of cases of disease or deaths
• Counts are Poisson distributed.
y ∼ P(µ)
Penalized-GLMM
• P-splines as mixed models:
I Linear Predictor:η = Bθ =⇒ Xβ + Zα
I Penalized log-Likelihood:
`p(β,α; y) = `(β,α; y)− 12α′Fα
I Estimation via PQL
Uc3m/ Dept. of Statistics 27First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
P-splines for spatial count dataI In many applications:
• Collect count data observed in regions or areas.• E.g.: # of cases of disease or deaths
• Counts are Poisson distributed.
y ∼ P(µ)
Penalized-GLMM
• P-splines as mixed models:
I Linear Predictor:η = Bθ =⇒ Xβ + Zα
I Penalized log-Likelihood:
`p(β,α; y) = `(β,α; y)− 12α′Fα
I Estimation via PQL
Uc3m/ Dept. of Statistics 27First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Most popular approach:
• Conditional AutoregressiveModels (CAR), Besag (1991)
• Spatial Dependence across“neighbours”.
• Different neighbourhoodcriteria.I Common border.I Centroids distance, 4-nearest
neighbours.
Uc3m/ Dept. of Statistics 28First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Most popular approach:
• Conditional AutoregressiveModels (CAR), Besag (1991)
• Spatial Dependence across“neighbours”.
• Different neighbourhoodcriteria.I Common border.I Centroids distance, 4-nearest
neighbours.
Uc3m/ Dept. of Statistics 28First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Most popular approach:
• Conditional AutoregressiveModels (CAR), Besag (1991)
• Spatial Dependence across“neighbours”.
• Different neighbourhoodcriteria.I Common border.I Centroids distance, 4-nearest
neighbours.
Uc3m/ Dept. of Statistics 28First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Most popular approach:
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• Conditional AutoregressiveModels (CAR), Besag (1991)
• Spatial Dependence across“neighbours”.
• Different neighbourhoodcriteria.I Common border.I Centroids distance, 4-nearest
neighbours.
Uc3m/ Dept. of Statistics 28First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Formulation:y = Xβ + b,
where b = (b1, b2, ..., bn)′ is a vector for the spatial effects
• Impose a spatial dependency structure by a prior distribution for b:
b ∼ N (0,Gb)
where Gb depends on the “neighbourhood structure”:
I defined by Contiguity matrix (Q)
Uc3m/ Dept. of Statistics 29First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
I Formulation:y = Xβ + b,
where b = (b1, b2, ..., bn)′ is a vector for the spatial effects
• Impose a spatial dependency structure by a prior distribution for b:
b ∼ N (0,Gb)
where Gb depends on the “neighbourhood structure”:
I defined by Contiguity matrix (Q)
Uc3m/ Dept. of Statistics 29First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
X We follow an Empirical Bayes approach:
I Intrinsic CAR:Gb = σ2
b Q− + κ−1I (Besag, 1991)
• Two independent and separate variance components:
I Spatially-structured variation: σ2b Q−
I Unstructured non-spatial correlation: κ−1I
I Alternative CAR models structures:
Gb = σ2b (φQ + (1− φ)I)−1 (Leroux et al, 1999)
Gb = σ2b (φQ− + (1− φ)I) (Dean et al, 2001)
where
I φ measures the relative weight between structured and unstructured variability
I 0 ≤ φ ≤ 1
Uc3m/ Dept. of Statistics 30First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelCAR model
X We follow an Empirical Bayes approach:
I Intrinsic CAR:Gb = σ2
b Q− + κ−1I (Besag, 1991)
• Two independent and separate variance components:
I Spatially-structured variation: σ2b Q−
I Unstructured non-spatial correlation: κ−1I
I Alternative CAR models structures:
Gb = σ2b (φQ + (1− φ)I)−1 (Leroux et al, 1999)
Gb = σ2b (φQ− + (1− φ)I) (Dean et al, 2001)
where
I φ measures the relative weight between structured and unstructured variability
I 0 ≤ φ ≤ 1
Uc3m/ Dept. of Statistics 30First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelLee and Durban (2009)
IWe propose a “hybrid” model:
• Spatial P-spline with CAR structure: “Smooth-CAR” model
• Model:η = Xβ + Zα + b ,
where b ∼ N (0,Gb)
Our approach:
η = Spatial Trend︸ ︷︷ ︸Xβ + Zα
+ Local area-level spatial correlation︸ ︷︷ ︸Spatial Random Effects
(Large-scale) (Small-scale)
Uc3m/ Dept. of Statistics 31First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR modelLee and Durban (2009)
IWe propose a “hybrid” model:
• Spatial P-spline with CAR structure: “Smooth-CAR” model
• Model:η = Xβ + Zα + b ,
where b ∼ N (0,Gb)
Our approach:
η = Spatial Trend︸ ︷︷ ︸Xβ + Zα
+ Local area-level spatial correlation︸ ︷︷ ︸Spatial Random Effects
(Large-scale) (Small-scale)
Uc3m/ Dept. of Statistics 31First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Smooth-CAR model
I Summary:
Model Linear Predictor Area-level var.Poisson Xβ + Zα −
CAR Xβ + b b ∼ N (0,Gb)Smooth-CAR Xβ + Zα + b b ∼ N (0,Gb)
I The Smooth-CAR:
I Allow us model the spatial trend (Xβ + Zα) along large geographical distances and
I Local area-level correlation by a CAR component (b).
Uc3m/ Dept. of Statistics 32First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer data
Example: Scottish Lip Cancer
• Breslow and Clayton (1993)
• Observed (y) and Expected (e)cases of lip cancer
• 56 counties in Scotland
• Period: 1975− 1980.
SCOTTISH LIP CANCER
OBSERVED EXPECTED
0
20
40
60
80
Uc3m/ Dept. of Statistics 33First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataFitted Models
IWe fit several models:
• Smooth P-splines models:
η = log(e) + Xβ + Zα (Poisson)
log(e) is the offset term.
• CAR models:η = log(e) + Xβ + b , b ∼ N (0,Gb),
with:
Gb = σ2b (φQ− + (1− φ)I) (Dean)
• Smooth-CAR model:
η = log(e) + Xβ + Zα + b , b ∼ N (0,Gb)
Uc3m/ Dept. of Statistics 34First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataFitted Models
IWe fit several models:
• Smooth P-splines models:
η = log(e) + Xβ + Zα (Poisson)
log(e) is the offset term.
• CAR models:η = log(e) + Xβ + b , b ∼ N (0,Gb),
with:
Gb = σ2b (φQ− + (1− φ)I) (Dean)
• Smooth-CAR model:
η = log(e) + Xβ + Zα + b , b ∼ N (0,Gb)
Uc3m/ Dept. of Statistics 34First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataFitted Models
IWe fit several models:
• Smooth P-splines models:
η = log(e) + Xβ + Zα (Poisson)
log(e) is the offset term.
• CAR models:η = log(e) + Xβ + b , b ∼ N (0,Gb),
with:
Gb = σ2b (φQ− + (1− φ)I) (Dean)
• Smooth-CAR model:
η = log(e) + Xβ + Zα + b , b ∼ N (0,Gb)
Uc3m/ Dept. of Statistics 34First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataModels comparison criteria
I In order to compare the proposed models we use:
AIC = Dev + 2× dfBIC = Dev + log(n)× df
where:
• df is the effective dimension of the model (“degrees of freedom”).
I is a measure of the complexity of the fitted model,I Calculated as the trace(H),
y = Hy
Uc3m/ Dept. of Statistics 35First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataModels comparison criteria
I In order to compare the proposed models we use:
AIC = Dev + 2× dfBIC = Dev + log(n)× df
where:
• df is the effective dimension of the model (“degrees of freedom”).
I is a measure of the complexity of the fitted model,I Calculated as the trace(H),
y = Hy
Uc3m/ Dept. of Statistics 35First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Application: Scottish Lip Cancer dataComparisons of fitted models
ParametersModel λ1 λ2 σ2
s κ−1 φ AIC BIC dfSmooth: Poisson 11.75 3.63 - - - 114.04 228.46 15.90
CAR: Dean - - 0.78 - 0.99 89.36 179.56 32.78Smooth-CAR: Dean 30.11 16.37 0.53 - 0.97 87.46 175.70 30.64
I Observations:
• φ ≈ 1 −→ Overdispersion is due to “structured” spatial correlation (σ2b Q−).
• Smooth-CAR performs better in terms of the selected criteria.
Uc3m/ Dept. of Statistics 36First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
I Dean’s CAR model:
(a) Linear Trend (b) CAR random effect (c) CAR
−1.0 −0.5 0.0 0.5 1.0 1.5
(a) Large-scale linear trend: Xβ
(b) CAR structured random effects: b ∼ N (0,Gb)
(c) Xβ + b
I Smooth-CAR model:
(a) Smooth Trend (b) CAR component (c) Trend+CAR
−1.0 −0.5 0.0 0.5 1.0 1.5
(a) Smooth large-scale spatial trend: Xβ + Zα
(b) CAR structured random effects: b ∼ N (0,Gb)
(c) Xβ + Zα + b
Spatio-temporal data Smoothing with P-splines
Outline
1 P-splinesMixed models approachMultidimensional P-splines
2 P-splines for spatial count dataSpatial smoothingSmooth-CAR modelApplication: Scottish Lip Cancer data
3 Spatio-temporal data Smoothing with P-splinesANOVA-Type Interaction ModelsApplication Environmental spatio-temporal data
4 Spatio-temporal Disease Mapping
Uc3m/ Dept. of Statistics 39First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines
Spatio-temporal data
• Response variable, yijt
• measured over geographical locations, s = (xi, xj), with i, j = 1, .., n
• and over time periods, xt, for t = 1, ....,T
• ISSUE: huge amount of data available• e.g. : Environmental data, epidemiologic studies, disease mapping
applications, ...
• Smoothing techniques:
• Study spatial and temporal trends.
• Space and time interactions.
X 3-dimensional smoothing: P-splines and GLAM.
Uc3m/ Dept. of Statistics 40First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines
Example of GLAM in 3dCurrie et. al (2006)
• 3d-case:f (x1, x2, x3) = Bθ
• Basis: B = B1 ⊗ B2 ⊗ B3
• θ can be expressed as a 3d-array A = {θ}ijk of dim. c1 × c2 × c3
θ(1,1,c3)θ(1,c2,c3)
θ(1,1,1)1,...,c2
columns
rows 1,...,c1
layer
1,...,c3
uuuuuuuuuθ(1,c2,1)
ttttttttt
θ(c1,1,c3)θ(c1,c2,c3)
θ(c1,1,1) θ(c1,c2,1)
ttttttttt
Uc3m/ Dept. of Statistics 41First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines
• 3d-Penalty matrix:
• Set penalties over the 3d-array A:
P = λ1 D′1D1 ⊗ Ic2 ⊗ Ic3︸ ︷︷ ︸row-wise
+λ2 Ic1 ⊗ D′2D2 ⊗ Ic3︸ ︷︷ ︸column-wise
+λt Ic1 ⊗ Ic2 ⊗ D′tDt︸ ︷︷ ︸layer-wise
• For spatio-temporal data:
f ( longitude, latitude︸ ︷︷ ︸Space
, time)
• Spatial anisotropy (λ1 6= λ2), different amount of smoothing for latitude andlongitude.
• Temporal smoothing (λt)
• Space-time interaction.
Uc3m/ Dept. of Statistics 42First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines
• For spatio-temporal data, we propose:
B-splines Basis:
B = Bs ⊗ Bt,
whereBs ≡ is the spatial B-spline basis (B1� B2) and
Bt ≡ is the B-spline basis for time of dim. t× c3.
X as GLAM:Given yijt = Yt×n, and θijt = Act×cs , we have
E[Y] = BtAB′s
X as Mixed models Bθ = Xβ + Zα
Uc3m/ Dept. of Statistics 43First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
Smooth-ANOVA decomposition models
• Chen (1993), Gu (2002):
• “Smoothing-Spline ANOVA” (SS-ANOVA).
• Interpretation as “main effects” and “interactions”.
• Models of type:
y = f (x1) + f (x2) + f (xt) “Main/additive effects”+f (x1, x2) + f (x1, xt) + f (x2, xt) “2-way interactions”+f (x1, x2, xt) “3-way interactions”
• PROBLEMS:• identifiability, and• basis dimension (“curse of dimensionality”)
Uc3m/ Dept. of Statistics 44First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
P-spline ANOVA modelfor spatio-temporal smoothing
• Lee and Durbán (2009a), consider:
y = γ + fs(x1, x2) + fs(time) + fst(x1, x2, time) + ε ,
wherefs(x1, x2) ≡ Spatial 2d smooth surface
ft(time) ≡ Smooth time trendfst(x1, x2, time) ≡ Space-time interaction
• We need to construct an identifiable model.
• Our approach is based on:• low-rank basis (P-splines)• the mixed model representation and SVD properties.
Uc3m/ Dept. of Statistics 45First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
Basis, Coefficients and Penalty
• For each smooth term f (·), in spatio-temporal ANOVA model we have
• B−spline basis:B = [1nt : Bs ⊗ 1t : 1n ⊗ Bt : Bs ⊗ Bt]
• vector of coefficients:
θ = (γ,θ(s)′ ,θ(t)′ ,θ(st)′)′
• and a blockdiagonal Penalty:
P =
0
Ps
Pt
Pst
,
where Ps = 2d-spatial penaltyPt = 1d-penalty for timePst = 3d space-time penalty
Uc3m/ Dept. of Statistics 46First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
Basis, Coefficients and Penalty
• For each smooth term f (·), in spatio-temporal ANOVA model we have
• B−spline basis:B = [1nt : Bs ⊗ 1t : 1n ⊗ Bt : Bs ⊗ Bt]
• vector of coefficients:
θ = (γ,θ(s)′ ,θ(t)′ ,θ(st)′)′
• and a blockdiagonal Penalty:
P =
0
Ps
Pt
Pst
,
where Ps = 2d-spatial penaltyPt = 1d-penalty for timePst = 3d space-time penalty
Uc3m/ Dept. of Statistics 46First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
Basis, Coefficients and Penalty
• For each smooth term f (·), in spatio-temporal ANOVA model we have
• B−spline basis:B = [1nt : Bs ⊗ 1t : 1n ⊗ Bt : Bs ⊗ Bt]
• vector of coefficients:
θ = (γ,θ(s)′ ,θ(t)′ ,θ(st)′)′
• and a blockdiagonal Penalty:
P =
0
Ps
Pt
Pst
,
where Ps = 2d-spatial penaltyPt = 1d-penalty for timePst = 3d space-time penalty
Uc3m/ Dept. of Statistics 46First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
Basis, Coefficients and Penalty
• For each smooth term f (·), in spatio-temporal ANOVA model we have
• B−spline basis:B = [1nt : Bs ⊗ 1t : 1n ⊗ Bt : Bs ⊗ Bt]
• vector of coefficients:
θ = (γ,θ(s)′ ,θ(t)′ ,θ(st)′)′
• and a blockdiagonal Penalty:
P =
0
Ps
Pt
Pst
,
where Ps = 2d-spatial penaltyPt = 1d-penalty for timePst = 3d space-time penalty
Uc3m/ Dept. of Statistics 46First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
X However, B is NOT full column-rank (“linear dependency”)
X Model is NOT identifiable
Solution:
• Reparameterize as a mixed model (using SVD).
• For each term we have:Basis [ X : Z ]
fs(x1, x2) ≡ x1 : x2 (1)
ft(xt) ≡ xt (2)
fst(x1, x2, xt) ≡ x1 : x2 : xt (3)
• Some terms in (1) and (2) also appear in (3).
Uc3m/ Dept. of Statistics 47First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
I The mixed model representation, allow us to identify the columns toremove in order to maintain the identifiability of the model.
and obtain a blockdiagonal penalty F
F =
08
FsFt
Fst
,
withλ1, λ2λtτ1, τ2, τt
I In P-splines context, this is equivalent toX apply constraints over regression coefficients θi,j,k
Uc3m/ Dept. of Statistics 48First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
I For the ANOVA spatio-temporal model, the resultant mixed modelreparameterization is equivalent to apply the next constraints:
• time effect coefficient: ∑ctt=1 θ
(t)t = 0,
• constraints over the spatio-temporal array of coefficients, Θ(st), ofdimensions ct × cs:
c1∑i
θ(st)t,ij =
c2∑j
θ(st)t,ij =
c1∑i
c2∑j
θ(st)t,ij = 0.
Uc3m/ Dept. of Statistics 49First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines ANOVA-Type Interaction Models
In practiceI We only need to construct the matrices X, Z and penalty F
fs(x1, x2) ft(xt) fst(x1, x2, xt)
X ≡ by columns x1 : x2 xt (x1, x2, xt)
Z ≡ by blocks ′′ ′′ ′′
F ≡ blockdiagonal Fs Ft Fst(λ1, λ2) λt (τ1, τ2, τt)
Uc3m/ Dept. of Statistics 50First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines Application Environmental spatio-temporal data
Ozone pollution in EuropeLee and Durbán (2009a)
• Sample of 45 monitoring stations
• Monthly averages of O3 levels (in µg/m3 units)
• from january 1999 to december 2005 (t = 1, ..., 84)
Models:
• Additive:fs(x1, x2) + ft(xt)
• Spatio-temporal Interaction:X ANOVA:
fs(x1, x2) + ft(xt) + fst(x1, x2, xt)
Uc3m/ Dept. of Statistics 51First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines Application Environmental spatio-temporal data
Spatial 2d + time
fs(x1, x2) + ft(xt)
0 5 10 15 20 25
4045
5055
6065
Latitude
Long
itude
40
50
60
70
80
90
1999 2000 2001 2002 2003 2004 2005
−20
−10
010
20year
f(tim
e)
X Space-time interaction is not considered
X time smooth trend is additive
Uc3m/ Dept. of Statistics 52First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines Application Environmental spatio-temporal data
Spatio-temporal ANOVA model
Play animation =
+ +
y f(space)
f(time)
1999 : 1
f(space,time)
Uc3m/ Dept. of Statistics 53First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines Application Environmental spatio-temporal data
Comparison of fitted valuesAdditive VS ANOVA
I Additive model fit I ANOVA model fitfs(x1, x2) + fs(xt) fs(x1, x2) + ft(xt) + fst(x1, x2, xt)
1999 2000 2001 2002 2003 2004 2005 2006
2040
6080
100
120
140
year
O3
SpainSwedenAustriaUK
1999 2000 2001 2002 2003 2004 2005 2006
2040
6080
100
120
140
year
O3
SpainSwedenAustriaUK
X Additive model assumes a spatial smooth surface over all monitoring stations that remainsconstant over time.
X ANOVA model captures individual characteristics of the stations throughout time.
Uc3m/ Dept. of Statistics 54First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal data Smoothing with P-splines Application Environmental spatio-temporal data
Comparison of ModelsANOVA and Additive
Model AIC dfANOVA 14280.73 366.03
Additive 16506.28 65.98
I Observations:
• Best overall performance of ANOVA in terms of AIC• ANOVA model is more realistic than Additive, and easier to decompose
and interpret in terms of the fit.
Uc3m/ Dept. of Statistics 55First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Outline
1 P-splinesMixed models approachMultidimensional P-splines
2 P-splines for spatial count dataSpatial smoothingSmooth-CAR modelApplication: Scottish Lip Cancer data
3 Spatio-temporal data Smoothing with P-splinesANOVA-Type Interaction ModelsApplication Environmental spatio-temporal data
4 Spatio-temporal Disease Mapping
Uc3m/ Dept. of Statistics 56First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Spatio-temporal Disease Mapping
P-spline ANOVA model for disease mapping
• Y and E are t× n arrays of observed and expected cases of disease over t timeperiods, and M = log( Y
E ).
• Consider an ANOVA model for η
fs(x1, x2) + ft(xt) + fst(x1, x2, xt)
−0.5
0.0
0.5
1.0
1.5
t1 t2 t3 t4 t5
t6 t7 t8 t9 t10
0
2
4
6
8
Uc3m/ Dept. of Statistics 57First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Summary
I New flexible approach for spatial and spatio-temporal data smoothing:
• based on P-splines as mixed models and• ANOVA decomposition
I Methodology also extensible for disease mapping applications.
I Computationally efficient algorithms (GLAM)
Uc3m/ Dept. of Statistics 58First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán
Bibliography
Lee, D.-J. and Durbán, M. (2009)Smooth-CAR mixed models for spatial count data.Computational Statistics and Data Analysis 53(8):2968-2979.
Lee, D.-J. and Durbán, M. (2009)P-spline ANOVA-Type interaction models for spatio-temporal smoothing.Submitted.
Eilers, PHC., Currie, ID. and Durbán, M. (2006)Fast and compact smoothing on large multidimensional grids.Computational Statistics and Data Analysis, 50(1):61-76.
Currie, ID., Durbán M. and Eilers, PHC. (2006)Generalized linear array models with applications to multidimensional smoothing.Journal of the Royal Statistical Society B, 68:1-22.
Uc3m/ Dept. of Statistics 59First Workshop on Spatio-temporal Disease Mapping, Valencia 2009
María Durbán