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Age × Stage-Classified Models

  • Hal Caswell
Open Access
Chapter
Part of the Demographic Research Monographs book series (DEMOGRAPHIC)

Abstract

The first step in developing any kind of structured population model is choosing one or more variables in terms of which to describe the population structure. The job of these i-state variables is to encapsulate all the information about the past experience of an individual that is relevant to its future behavior (Metz and Diekmann 1986; Caswell 2001).

6.1 Introduction

The first step in developing any kind of structured population model is choosing one or more variables in terms of which to describe the population structure. The job of these i-state variables is to encapsulate all the information about the past experience of an individual that is relevant to its future behavior (Metz and Diekmann 1986; Caswell 2001). Classical demography (for both humans and for non-human animals and plants) uses age as a i-state, but other, more biologically relevant criteria (e.g., size, developmental stage, parity, physiological condition, etc.) are now widely used in ecology, with age-classified models viewed as a special case.

However, it has long been recognized that cases exist where it is important to classify individuals by both age and stage.
  1. 1.

    Even in a stage-classified model, age still exists; every individual becomes older, by one unit of age, with the passage of each unit of time (e.g., Feichtinger 1971a; Caswell 2001, 2006, 2009; Tuljapurkar and Horvitz 2006; Horvitz and Tuljapurkar 2008). In these analyses, age dependence is implicit in the stage-classified model (see Chap.  5). Models that include both age and stage provide information that goes beyond this implicit dependence.

     
  2. 2.

    If the vital rates depend on both age and stage, only a model that includes both can reveal the joint action of age-and stage-specific processes (e.g., Goodman 1969). Such models, of course, require information on the joint age-dependence and stage-dependence of the vital rates, and thus are challenging to construct. A special case that has been extensively explored is the multi-regional case, in which the stage variable describes spatial location (e.g., Rogers 1966; Lebreton 1996). Models that combine age and some measure of health or disability status are an important part of health demography (e.g., Willekens 2014; Peeters et al. 2002; Wu et al. 2006; Zhou et al. 2016).

     

This chapter presents a model framework in which individuals are classified by age and stage, using the vec-permutation matrix approach (so-called for the role that the vec-permutation matrix plays in rearranging age and stage categories in the population vector). This formalism was introduced by Hunter and Caswell (2005) for populations classified by stage and location, was used in Chap.  5 to classify individuals by stage and environmental state; it has also been applied to stage and infection status (Klepac and Caswell 2011), stage and age (Caswell 2012; Caswell et al. 2018), and age and frailty (Caswell 2014). Megamatrix models (e.g., Pascarella and Horvitz 1998; Horvitz and Tuljapurkar 2008) can be written using this approach, as can block-structured multiregional models (e.g., Rogers 1975; Lebreton 1996). Matrix models can describe both population dynamics and cohort dynamics. Population dynamics (population growth, age and stage structure, reproductive value) depend on both the transitions of extant individuals and the production of new individuals by reproduction. In contrast, cohort dynamics (survivorship, life expectancy, age at death, generation time) depend only on the fates of already existing individuals. This chapter describes both kinds of analysis. For a more complete review and treatment, see Caswell et al. (2018).

6.2 Model Construction

The construction and analysis of these models requires a number of different matrices and operators (some of the notation is collected in Table 6.1). Individuals are classified into stages 1, …, s and age classes 1, …, ω. The model treats the processes of moving among stages and moving among age classes as alternating. First, stage-specific demography operates to move individuals among stages and to produce new offspring, with rates appropriate to their ages. Then aging acts to move individuals to the next older age, and the process repeats.
Table 6.1

Mathematical notation used in this chapter. Dimensions are shown, where relevant, for matrices and vectors; s denotes the number of stages and ω the number of age classes

Quantity

Description

Dimension

Ai, Fi, Ui

Stage-classified projection, fertility, and transition matrices for age class i

s × s

DU, DF

Age transition matrices for individuals already present in the population and for new individuals produced by reproduction

ω × ω

\(\mathbb {A,F,U,D}\)

Block-diagonal matrices

 × 

\(\tilde {{\mathbf {A}}}, \tilde {{\mathbf {U}}}\), etc.

Age × stage matrices constructed from block-diagonal matrices using the vec-permutation matrix

 × 

Ks,ω, K

Vec-permutation matrix

 × 

I s

Identity matrix

s × s

1 s

Vector of ones

s × 1

e i

The ith unit vector, with a 1 in the ith entry and zeros elsewhere

Various

E ij

A matrix with a 1 in the (i, j) position, and zeros elsewhere

Various

Kronecker product

 

Hadamard, or element-by-element, product

 

vec X

The vec operator, which stacks the columns of a m × n matrix X into a mn × 1 vector

 

\(\mathcal {D}\,({\mathbf {x}})\)

A diagonal matrix with x on the diagonal and zeros elsewhere

 
Define a stage-classified projection matrix Ai, of dimension s × s, for each age class, i = 1, …, ω. Decompose Ai into
$$\displaystyle \begin{aligned} {\mathbf{A}}_i = {\mathbf{U}}_i + {\mathbf{F}}_i \end{aligned} $$
(6.1)
where Ui contains the transition probabilities of extant individuals and Fi describes the generation of new individuals by reproduction.
Aging is described by two matrices, each of dimension ω × ω (shown here for 3 × 3, but easily generalized),
$$\displaystyle \begin{aligned} \begin{array}{rcl} {\mathbf{D}}_{\mathrm{U}} &=& \left(\begin{array}{ccc} 0 & 0 & 0 \\ 1 & 0 & 0 \\ 0 & 1 & 1 \end{array}\right) \qquad \mbox{dimension } \omega \times \omega {} \end{array} \end{aligned} $$
(6.2)
$$\displaystyle \begin{aligned} \begin{array}{rcl} {\mathbf{D}}_{\mathrm{F}} &=& \left(\begin{array}{ccc} 1 & 1 & 1 \\ 0 & 0 & 0 \\ 0 & 0 & 0 \end{array}\right) \qquad \omega \times \omega {} \end{array} \end{aligned} $$
(6.3)
The matrix DU applies to extant individuals; such an individual advances to the next age class. I have set the (ω, ω) entry of DU to 1, so that the last age class contains individuals of age ω and older. If this entry were set to 0, all individuals in the last age class would die. The matrix DF applies to individuals newly created by reproduction; such newborn individuals are placed in the first age class, regardless of the age of their parents.
Using the matrices Ai, Ui, Fi, DU, and DF, construct block-diagonal matrices, each of dimension  × . For example,
$$\displaystyle \begin{aligned} \mathbb{A} = \left(\begin{array}{ccc} {\mathbf{A}}_1 & & \\ & \ddots & \\ & & {\mathbf{A}}_{\omega} \end{array}\right)\end{aligned} $$
(6.4)
with similar structures for \(\mathbb {U}\), \(\mathbb {F}\), \(\mathbb {D}_{\mathrm {U}}\), and \(\mathbb {D}_{\mathrm {F}}\). These block-diagonal matrices can be written
$$\displaystyle \begin{aligned} \begin{array}{rcl} \mathbb{A} &\displaystyle =&\displaystyle \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{A}}_i \right) {} \end{array} \end{aligned} $$
(6.5)
$$\displaystyle \begin{aligned} \begin{array}{rcl} \mathbb{U} &\displaystyle =&\displaystyle \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{U}}_i \right) {} \end{array} \end{aligned} $$
(6.6)
$$\displaystyle \begin{aligned} \begin{array}{rcl} \mathbb{F} &\displaystyle =&\displaystyle \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{F}}_i \right) {} \end{array} \end{aligned} $$
(6.7)
$$\displaystyle \begin{aligned} \begin{array}{rcl} \mathbb{D}_{\mathrm{U}} &\displaystyle =&\displaystyle {\mathbf{I}}_s \otimes {\mathbf{D}}_{\mathrm{U}} {} \end{array} \end{aligned} $$
(6.8)
$$\displaystyle \begin{aligned} \begin{array}{rcl} \mathbb{D}_{\mathrm{F}} &\displaystyle =&\displaystyle {\mathbf{I}}_s \otimes {\mathbf{D}}_{\mathrm{F}} {}\vspace{-3pt} \end{array} \end{aligned} $$
(6.9)
where Eii is of dimension ω × ω.
If the demography is strictly stage-dependent, so that Ai = A, for i = 1, …, ω, then the block-diagonal matrices \(\mathbb {A}\), \(\mathbb {F}\), and \(\mathbb {U}\) reduce to, e.g.,
$$\displaystyle \begin{aligned} \mathbb{A} = {\mathbf{I}}_{\omega} \otimes {\mathbf{A}} {}\end{aligned} $$
(6.10)
with corresponding expressions for \(\mathbb {F}\) and \(\mathbb {U}\).
The state of the population at time t could be described by a 2-dimensional array
$$\displaystyle \begin{aligned} \boldsymbol{\mathcal{ N}}(t) = \left(\begin{array}{ccc} n_{11} & \cdots & n_{1 \omega} \\ \vdots & & \vdots \\ n_{s1} & \cdots & n_{s \omega} \end{array}\right) (t) \qquad s \times \omega\end{aligned} $$
(6.11)
where rows correspond to stages and columns to age classes. However, such a 2-dimensional array cannot be projected directly; instead, it is transformed to a vector, using the vec operator, which stacks the columns of the matrix one above the next. The vector n(t) created in this way contains the stages arranged within age classes. An alternative configuration, with ages arranged within stages, is obtained by applying the vec operator to \(\boldsymbol {\mathcal { N}}^{\mathsf {T}}\): The two vectors \(\mbox{vec} \, \boldsymbol {\mathcal { N}}\) and \(\mbox{vec} \,\boldsymbol {\mathcal { N}}^{\mathsf {T}}\) are related by the vec-permutation matrix, or commutation matrix, K, (Henderson and Searle 1981),
$$\displaystyle \begin{aligned} \mbox{vec} \,\boldsymbol{\mathcal{ N}}^{\mathsf{T}} = {\mathbf{K}}_{s, \omega} \mbox{vec} \, \boldsymbol{\mathcal{ N}} \end{aligned} $$
(6.14)
(see Sect.  2.2.3). Where no confusion seems likely to arise, we will suppress the subscripts and write Ks,ω as K. As with any permutation matrix, KT = K−1.
The goal of the model is to project the age-stage vector \({\mathbf {n}} = \mbox{vec} \,\boldsymbol {\mathcal { N}}\) from t to t + 1. The complete projection is given by
$$\displaystyle \begin{aligned} {\mathbf{n}}(t+1) = \left( \rule{0in}{3ex} {\mathbf{K}}^{\mathsf{T}} \mathbb{D}_{\mathrm{U}} {\mathbf{K}} \mathbb{U} + {\mathbf{K}}^{\mathsf{T}} \mathbb{D}_{\mathrm{F}} {\mathbf{K}} \mathbb{F} \right) {\mathbf{n}}(t) {} \end{aligned} $$
(6.15)
This deserves some explanation. Consider the first term on the right hand side, \({\mathbf {K}}^{\mathsf {T}} \mathbb {D}_{\mathrm {U}} {\mathbf {K}} \mathbb {U}\). Reading from right to left, it first operates on the vector n(t) with the block diagonal matrix \(\mathbb {U}\), which moves surviving extant individuals among stages without changing their age. Then the resulting vector is rearranged by the vec-permutation matrix K to group individuals by age classes within each stage. The block diagonal matrix \(\mathbb {D}_{\mathrm {U}}\) then moves each surviving individual to the next older age class. Finally, KT rearranges the vector back to the stage-within-age arrangement of n(t).

The second term in (6.15), \( {\mathbf {K}}^{\mathsf {T}} \mathbb {D}_{\mathrm {F}} {\mathbf {K}} \mathbb {F} \), carries out a similar sequence of transformations for the generation of new individuals. First, newborn individuals are produced according to the block-diagonal fertility matrix \(\mathbb {F}\). The resulting vector is rearranged by the vec-permutation matrix, and then the matrix \(\mathbb {D}_{\mathrm {F}}\) places all the newborn individuals into the first age class. Finally, KT rearranges the vector to the stage-within-age arrangement.

I will write the age × stage projection matrix in (6.15) as
$$\displaystyle \begin{aligned} \begin{array}{rcl} \tilde{{\mathbf{A}}} &\displaystyle =&\displaystyle \left( \rule{0in}{3ex} {\mathbf{K}}^{\mathsf{T}} \mathbb{D}_{\mathrm{U}} {\mathbf{K}} \mathbb{U} + {\mathbf{K}}^{\mathsf{T}} \mathbb{D}_{\mathrm{F}} {\mathbf{K}} \mathbb{F} \right) {} \end{array} \end{aligned} $$
(6.16)
$$\displaystyle \begin{aligned} \begin{array}{rcl} &\displaystyle =&\displaystyle \left( \tilde{{\mathbf{U}}} + \tilde{{\mathbf{F}}} \right) \end{array} \end{aligned} $$
(6.17)
The matrices \(\tilde {{\mathbf {A}}}\), \(\tilde {{\mathbf {U}}}\), and \(\tilde {{\mathbf {F}}}\) that operate on the age-stage vector n are denoted with a tilde (\(\tilde {{\mathbf {A}}}\), \(\tilde {{\mathbf {U}}}\), \(\tilde {{\mathbf {F}}}\)); these matrices define the age × stage-classified model and can be subjected to all the usual demographic analyses.

6.3 Sensitivity Analysis

Age-stage models pose particular challenges for perturbation analysis, because interest naturally focuses on changes in the matrices Fi and Ui (i = 1, …, ω), which are deeply embedded within \(\tilde {{\mathbf {F}}}\), \(\tilde {{\mathbf {U}}}\), and \(\tilde {{\mathbf {A}}}\).

Consider a generic dependent variable ξ, which is a scalar- or vector-valued function of \(\tilde {{\mathbf {A}}}\). In the examples to follow, ξ will be either the population growth rate λ or the joint distribution of age and stage at death in a cohort, but it could be any variable calculated from \(\tilde {{\mathbf {A}}}\). Let θ be a vector of parameters; these could be entries of the matrices, or lower-level parameters determining those entries. The goal of perturbation analysis is to obtain the derivative of ξ with respect to θ,
$$\displaystyle \begin{aligned} {d \boldsymbol{\xi} \over d \boldsymbol{\theta}^{\mathsf{T}}} = {d \boldsymbol{\xi} \over d \mbox{vec} \,^{\mathsf{T}} \tilde{{\mathbf{A}}}} \; {d \mbox{vec} \, \tilde{{\mathbf{A}}} \over d \boldsymbol{\theta}^{\mathsf{T}}}. {} \end{aligned} $$
(6.18)
The first term in (6.18) is the derivative of ξ with respect to the matrix \(\tilde {{\mathbf {A}}}\). If, for example, ξ was the dominant eigenvalue λ, then this term would be the matrix calculus version of the well-known eigenvalue sensitivity equation.
The second term in (6.18) requires differentiating \(\tilde {{\mathbf {A}}}\) with respect to the parameters that determine it. From (6.16), write
$$\displaystyle \begin{aligned} \tilde{{\mathbf{A}}} = {\mathbf{Q}}_{\mathrm{U}} \mathbb{U} + {\mathbf{Q}}_{\mathrm{F}} \mathbb{F} {} \end{aligned} $$
(6.19)
where \({\mathbf {Q}}_{\mathrm {U}} = {\mathbf {K}}^{\mathsf {T}} \mathbb {D}_{\mathrm {U}} {\mathbf {K}}\) and \({\mathbf {Q}}_{\mathrm {F}} = {\mathbf {K}}^{\mathsf {T}} \mathbb {D}_{\mathrm {F}} {\mathbf {K}}\) are the (constant) matrix products appearing in the definition of \(\tilde {{\mathbf {U}}}\) and \(\tilde {{\mathbf {F}}}\) in (6.16).
Differentiating \(\tilde {{\mathbf {A}}}\) in (6.19) gives
$$\displaystyle \begin{aligned} d \mbox{vec} \, \tilde{{\mathbf{A}}} = \left( {\mathbf{I}}_{sw} \otimes {\mathbf{Q}}_{\mathrm{U}} \right) d \mbox{vec} \, \mathbb{U} + \left( {\mathbf{I}}_{sw} \otimes {\mathbf{Q}}_{\mathrm{F}} \right) d \mbox{vec} \, \mathbb{F} {} \end{aligned} $$
(6.20)
This requires the differentials of \(\mathbb {U}\) and \(\mathbb {F}\). Differentiating \(\mathbb {U}\) in (6.6) gives
$$\displaystyle \begin{aligned} d \mathbb{U} = \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes d {\mathbf{U}}_i \right) \end{aligned} $$
(6.21)
Applying the vec operator to \(d \mathbb {U}\) gives
$$\displaystyle \begin{aligned} d \mbox{vec} \, \mathbb{U} = \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) d \mbox{vec} \, {\mathbf{U}}_i {} \end{aligned} $$
(6.22)
using the results of Magnus and Neudecker (1985, Theorem 11); see also Klepac and Caswell (2011, Appendix B) on the derivative of the Kronecker product. Differentiation of \(\mathbb {F}\) proceeds in the same fashion, yielding
$$\displaystyle \begin{aligned} d \mbox{vec} \, \mathbb{F} = \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) d \mbox{vec} \, {\mathbf{F}}_i {} \end{aligned} $$
(6.23)
In the special case where \(\mathbb {U}\) and \(\mathbb {F}\) are constructed from single stage-classified matrices U and F, as in (6.10), Eqs. (6.22) and (6.23) simplify even further to
$$\displaystyle \begin{aligned} \begin{array}{rcl} d \mbox{vec} \, \mathbb{U} &\displaystyle =&\displaystyle \left( {\mathbf{I}}_\omega \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) d \mbox{vec} \, {\mathbf{U}} \end{array} \end{aligned} $$
(6.24)
$$\displaystyle \begin{aligned} \begin{array}{rcl} d \mbox{vec} \, \mathbb{F} &\displaystyle =&\displaystyle \left( {\mathbf{I}}_\omega \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) d \mbox{vec} \, {\mathbf{F}} \end{array} \end{aligned} $$
(6.25)
Substituting (6.22) and (6.23) into (6.20) and then substituting (6.20) into (6.18) yields the general result for the derivative
$$\displaystyle \begin{aligned} \begin{array}{rcl} {d \boldsymbol{\xi} \over d \boldsymbol{\theta}^{\mathsf{T}}} &\displaystyle =&\displaystyle {d \boldsymbol{\xi} \over d \mbox{vec} \,^{\mathsf{T}} \tilde{{\mathbf{A}}}} \left[ \rule{0in}{3.5ex} \left( {\mathbf{I}}_{sw} \otimes {\mathbf{Q}}_{\mathrm{U}} \right) \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) {d \mbox{vec} \, {\mathbf{U}}_i \over d \boldsymbol{\theta}^{\mathsf{T}}} \right] \\ {} &\displaystyle +&\displaystyle {d \boldsymbol{\xi} \over d \mbox{vec} \,^{\mathsf{T}} \tilde{{\mathbf{A}}}} \left[ \rule{0in}{3.5ex} \rule{0in}{2.5ex} \left( {\mathbf{I}}_{sw} \otimes {\mathbf{Q}}_{\mathrm{F}} \right) \sum_{i=1}^\omega \left( {\mathbf{E}}_{ii} \otimes {\mathbf{K}} \otimes {\mathbf{I}}_s \right) \left( \mbox{vec} \, {\mathbf{I}}_\omega \otimes {\mathbf{I}}_{s^2} \right) {d \mbox{vec} \, {\mathbf{F}}_i \over d \boldsymbol{\theta}^{\mathsf{T}}} \right]\\ {} \end{array} \end{aligned} $$
(6.26)

Notice that (6.26) requires only three pieces of demographic information: the derivatives of Ui and Fi with respect to the parameters (whatever those may be in the case at hand) and the sensitivity of the dependent variable ξ (whatever that may be) to the elements of the matrix \(\tilde {{\mathbf {A}}}\) from which it is calculated. All the other pieces of (6.26) are constants. Some of these constant matrices may be large, depending on s and ω, but they are very sparse; the sparse matrix technology available in Matlab can be extremely useful in implementation. An alternative formulation of the differentials of the block matrices \(\mathbb {U}\) and \(\mathbb {F}\) is given in Caswell and van Daalen (2016).

6.4 Examples

Here we consider two examples of the sensitivity analysis of age-stage model to extract age-classified information from a stage-classified model. The first example will derive the sensitivity of the population growth rate λ, obtaining the sensitivity of λ to both age- and stage-specific survival, permitting examination of how selection pressures on senescence-inducing traits would vary from stage to stage. The second example is an analysis of the joint distribution of age and stage at death.

These examples are based on a stage-classified model (Parker 2000) for Scotch broom (Cytisus scoparius). Scotch broom is a large (up to 4 m tall) leguminous shrub, introduced into North America from Europe in the late nineteenth century. It is an invasive plant, considered a pest in the northwestern parts of North America. Stage-classified demographic models have been used to evaluate potential management policies for the plant (Parker 2000) and to investigate its potential for spatial spread (Neubert and Parker 2004).

The model contains seven stages (stage 1 = seeds, 2 = seedlings, 3 = juveniles, 4 = small adults, 5 = medium adults, 6 = large adults, 7 = extra-large adults), and parameters were estimated at a number of locations in Washington State. As is typical with many perennial plant species, survival is low for seeds and seedlings, but increases dramatically in larger stages. Parker’s study presented estimated projection matrices for plants at the edge, at intermediate locations, and at the center of an invading stand. Plants near the center experience more crowding, with resulting reduced rates of survival, growth, and fertility.

6.4.1 Population Growth Rate and Selection Gradients

The population growth rate λ, the stable age or stage distribution w, and age or stage-specific reproductive value vector v are given by the dominant eigenvalue and corresponding right and left eigenvectors of the population projection matrix, respectively. In evolutionary demography, λ measures the fitness of a phenotype, in that it gives the eventual rate at which descendants of an individual with that phenotype will increase. The selection gradient on a vector of traits θ is given by
$$\displaystyle \begin{aligned} {d \lambda \over d \boldsymbol{\theta}^{\mathsf{T}}} \end{aligned} $$
(6.27)
These gradients play a fundamental role in evolutionary biodemography, whether evolution is conceived of in terms of population genetics, quantitative genetics, adaptive dynamics, or mutation accumulation (e.g., Metz et al. 1992; Dercole and Rinaldi 2008; Rice 2004; Barfield et al. 2011). If the gradient is positive, selection favors an increase in the trait, and vice-versa.
In this application, ξ in (6.18) is the dominant eigenvalue λ. Let w and v be the right and left eigenvectors corresponding to λ, scaled so that vTw = 1. Then, in (6.26),
$$\displaystyle \begin{aligned} {d \lambda \over d \mbox{vec} \,^{\mathsf{T}} \tilde{{\mathbf{A}}}} = {\mathbf{w}}^{\mathsf{T}} \otimes {\mathbf{v}}^{\mathsf{T}}. {} \end{aligned} $$
(6.28)
See Chap.  3 and Caswell (2010).
In this model, the vital rates are functions only of stage; the phenotype is blind to the age of the individual. However, the terms in the summations in (6.26) give the selection gradients on traits that would modify the phenotype at each age. That is, Thus, these terms reveal the selection patterns that would operate on a mutation that was able to detect the age of an individual within a given stage, or that affected age differentially depending on the stage of the individual.
To examine the selection gradients on survival, it is necessary to separate survival from inter-stage transitions in U. Let σ be the vector of stage-specific survival probabilities. The matrix U can be written as the product of a matrix Σ = 1sσT containing the survival probabilities on the diagonal and a matrix G of transition probabilities, conditional on survival;
$$\displaystyle \begin{aligned} {\mathbf{U}} = {\mathbf{G}} \boldsymbol{\Sigma}. \end{aligned} $$
(6.30)
(cf. Chap.  8). If F is independent1 of σ, then
$$\displaystyle \begin{aligned} d {\mathbf{U}} = {\mathbf{G}} \; d \boldsymbol{\Sigma}. \end{aligned} $$
(6.31)
Applying the vec operator gives
$$\displaystyle \begin{aligned} \begin{array}{rcl} d \mbox{vec} \, {\mathbf{U}} &\displaystyle =&\displaystyle \left( {\mathbf{I}}_s \otimes {\mathbf{G}} \right) \mbox{vec} \, \mathcal{D}\,({\mathbf{1}}_s d \boldsymbol{\sigma}^{\mathsf{T}}) \\ &\displaystyle =&\displaystyle \left( {\mathbf{I}}_s \otimes {\mathbf{G}} \right) \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_s \right) \left( {\mathbf{I}}_s \otimes {\mathbf{1}}_s \right) d \boldsymbol{\sigma} \end{array} \end{aligned} $$
(6.32)
which implies that
$$\displaystyle \begin{aligned} {d \mbox{vec} \, {\mathbf{U}} \over d \boldsymbol{\sigma}^{\mathsf{T}}} = \left( {\mathbf{I}}_s \otimes {\mathbf{G}} \right) \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_s \right) \left( {\mathbf{I}}_s \otimes {\mathbf{1}}_s \right) {} \end{aligned} $$
(6.33)
Setting θ = σ and substituting (6.33) and (6.28) into (6.18) gives the selection gradient on σ. Substituting (6.33) and (6.28) into (6.29), with dvec FdθT = 0, gives the selection gradient on σ as a function of age and stage.

Results

The projection matrix A for Scotch broom2 is
$$\displaystyle \begin{aligned} {\mathbf{A}} = \left(\begin{array}{ccccccc} 0.740 & 0 & 3.400 & 47.1 & 108.700 & 1120.0 & 3339.0 \\ 0.001 & 0.310 & 0 & 0 & 0 & 0 & 0 \\ 0 & 0.350 & 0.310 & 0 & 0 & 0 & 0 \\ 0 & 0.038 & 0.290 & 0.024 & 0 & 0 & 0 \\ 0 & 0 & 0.069 & 0.390 & 0.320 & 0 & 0.091 \\ 0 & 0 & 0 & 0.440 & 0.440 & 0.530 & 0.091 \\ 0 & 0 & 0 & 0 & 0.029 & 0.400 & 0.730 \end{array}\right) {} \end{aligned} $$
(6.34)

The matrix U is obtained from A by setting all elements in the first row, except for a11, to zero. The matrix F is a 7 × 7 matrix with the elements of row 1, columns 2–7 of A in the corresponding positions, and zeros elsewhere. The maximum age was set to ω = 30. The aging matrices DU and DF are given by (6.2) and (6.3) with ω = 30. Because the vital rates do not depend on age, the dominant eigenvalues of A and \(\tilde {{\mathbf {A}}}\) should be identical, and they are; λ = 1.268.

The selection gradients on stage-specific survival (i.e., sensitivities of λ to σ) are shown in Fig. 6.1. There is a steady decline with increasing stage, from seeds to medium-sized adults, but then an increase for large and extra-large adults. A quite different pattern emerges when the selection gradients are calculated as functions of both age and stage, using (6.29). These results are shown in Fig. 6.2. The age-specific selection gradients on survival in stages 1–3 are strictly decreasing with age. But the age-specific selection gradients on survival in the adult stages 4–7 increase with age, level off, and then decline. The increase is longer and more pronounced in the larger adult stages.
Fig. 6.1

Sensitivity of population growth rate λ to stage-specific survival probabilities. Calculated for the stage-classified model of Scotch broom (Cytisus scoparius) using data from Parker (2000). Stages: 1 = seeds, 2 = seedlings, 3 = juveniles, 4 = small adults, 5 = medium adults, 6 = large adults, 7 = extra-large adults

Fig. 6.2

Sensitivity of population growth rate λ to stage-specific survival as a function of age, for Scotch broom. Stages defined as in Fig. 6.1

It is now known that this pattern is widespread in plant populations. It appears in all eight of the Scotch broom populations studied by Parker (2000), and in almost all of 36 species of plants examined by Caswell and Salguero-Gómez (2013). It has important implications for the evolution of senescence. Hamilton (1966) showed that the selection gradient on age-specific mortality is always decreases with age, and argued that this implied that selection would always lead to senescence. Incorporating stage-dependence as well as age-dependence of the vital rates means that, over some range of ages, the selection gradient increases (contra-senescent selection in the terminology of Caswell and Salguero-Gómez 2013). Thus conclusions that follow from the general decline in selection gradients with age may not apply to traits that affect age-specific survival differentially depending on developmental stage. Traits that affect survival in adult stages should postpone senescence for at least some time.

6.4.2 Distributions of Age and Stage at Death

The pattern of longevity within a population is captured by the probability distribution of the age at death, one of the standard results of age-classified life table analysis. The moments of the age at death and their sensitivity can also be calculated directly from stage-classified models using Markov chain methods (Feichtinger 1971b; Caswell 2001, 2006, 2009; Tuljapurkar and Horvitz 2006; Horvitz and Tuljapurkar 2008); see Chaps.  4 and  5. Here we can go beyond that and get the full joint distribution of stage and age at death, along with the marginal distributions of age at death and stage at death, implied by an age × stage classified model.

To do this, note that the cohort projection matrix \(\tilde {{\mathbf {U}}}\) describes movement of individuals among transient states of an absorbing Markov chain, where the absorbing state is death, or death classified by stage or age at death. The transition matrix of the chain is By properly structuring M, the model can give information about the age, stage, or the joint distribution of age and stage at death.3 Each row of \(\tilde {{\mathbf {M}}}\) corresponds to an absorbing state, and \(\tilde m_{ij}\) is the probability of a transition from transient state j to absorbing state i. To compute the distribution of age and stage at death, we define the absorbing states to correspond to the age × stage combination at death. Thus \(\tilde {{\mathbf {M}}}\) contains probabilities of death on the diagonal and zeros elsewhere,
$$\displaystyle \begin{aligned} \tilde{{\mathbf{M}}} = {\mathbf{I}}_{s \omega} - \mathcal{D}\, \left( {\mathbf{1}}_{s \omega}^{\mathsf{T}} \tilde{{\mathbf{U}}} \right). {} \end{aligned} $$
(6.36)
The fundamental matrix of the Markov chain in (6.35) is
$$\displaystyle \begin{aligned} \tilde{{\mathbf{N}}} = \left( {\mathbf{I}} - \tilde{{\mathbf{U}}} \right) ^{-1} \end{aligned} $$
(6.37)
The (i, j) element of \(\tilde {{\mathbf {N}}}\) is the expected number of visits that an individual in state j will make to transient state i before death.
Consider the eventual fate of an individual starting in transient state j. Let
$$\displaystyle \begin{aligned} \tilde b_{ij} = P \left[ \mbox{eventual absorption in }i \; | \; \mbox{starting in }j \right] \end{aligned} $$
(6.38)
The \(\tilde b_{ij}\) are the elements of the matrix \(\tilde {{\mathbf {B}}}\) ( × ) given by
$$\displaystyle \begin{aligned} \tilde{{\mathbf{B}}} = \tilde{{\mathbf{M}}} \tilde{{\mathbf{N}}}\vspace{-3pt} {} \end{aligned} $$
(6.39)
(Iosifescu 1980, Theorem 3.3; see also Caswell 2001, Section 5.1). Since the absorbing states (the rows of \(\tilde {{\mathbf {M}}}\)) correspond to combinations of age and stage at death, column j of \(\tilde {{\mathbf {B}}}\) gives the joint distribution of age and stage at death, starting from state (i.e., age × stage combination) j:
$$\displaystyle \begin{aligned} \tilde{{\mathbf{B}}}(:,j) = \tilde{{\mathbf{B}}} {\mathbf{e}}_j {}\end{aligned} $$
(6.40)
using Matlab notation in which X(:, j) is column j of X, and where ej is a vector of length with a 1 in the jth entry and zeros elsewhere. The rows of \(\tilde {{\mathbf {B}}}\) correspond to combinations of stage and age at death. Summing the rows over stages gives the marginal distribution of age at death, starting in column j of \(\tilde {{\mathbf {B}}}\), as
$$\displaystyle \begin{aligned} {\mathbf{g}}_j = \left( {\mathbf{I}}_\omega \otimes {\mathbf{1}}_s^{\mathsf{T}} \right) \tilde{{\mathbf{B}}}(:,j) \qquad \mbox{marginal age distribution} \qquad \omega \times 1 \end{aligned} $$
(6.41)
Similarly, summing over ages gives the marginal distribution of stage at death:
$$\displaystyle \begin{aligned} {\mathbf{h}}_j = \left({\mathbf{1}}_\omega^{\mathsf{T}} \otimes {\mathbf{I}}_s \right) \tilde{{\mathbf{B}}}(:,j) \qquad \mbox{marginal stage distribution} \qquad s \times 1 \end{aligned} $$
(6.42)

6.4.2.1 Perturbation Analysis

In the general sensitivity equation (6.18), the dependent variable \(\boldsymbol {\xi } = \tilde {{\mathbf {B}}}(:,j)\). This depends only on \(\tilde {{\mathbf {U}}}\), so the first term in (6.18) can be shown to be
$$\displaystyle \begin{aligned} \begin{array}{rcl} {d \boldsymbol{\xi} \over d \mbox{vec} \, \tilde{{\mathbf{A}}}} &\displaystyle =&\displaystyle {d \tilde{{\mathbf{B}}}(:,j) \over d \mbox{vec} \, \tilde{{\mathbf{U}}}} \end{array} \end{aligned} $$
(6.43)
$$\displaystyle \begin{aligned} \begin{array}{rcl} &\displaystyle =&\displaystyle - \left( {\mathbf{e}}_j^{\mathsf{T}} \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_{s \omega} \right) \left( {\mathbf{I}}_{s \omega} \otimes {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \right) + \left( {\mathbf{e}}_j^{\mathsf{T}} \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes \tilde{{\mathbf{B}}} \right)\\ {}\vspace{-3pt} \end{array} \end{aligned} $$
(6.44)
The desired derivative \(d \tilde {{\mathbf {B}}}(:,j)/ d \boldsymbol {\theta }^{\mathsf {T}}\) is obtained by substituting (6.44) for \(d \boldsymbol {\xi } / d \mbox{vec} \, \tilde {{\mathbf {A}}}\) in (6.26), setting dvec FidθT = 0.
The sensitivities of the marginal distributions of age and stage at death are then given by
$$\displaystyle \begin{aligned} \begin{array}{rcl} {d {\mathbf{g}}_j \over d \boldsymbol{\theta}^{\mathsf{T}}} &\displaystyle =&\displaystyle \left( {\mathbf{I}}_\omega \otimes {\mathbf{1}}^{\mathsf{T}}_s \right) {d \tilde{{\mathbf{B}}}(:,j) \over d \boldsymbol{\theta}^{\mathsf{T}}} {} \end{array} \end{aligned} $$
(6.45)
$$\displaystyle \begin{aligned} \begin{array}{rcl} {d {\mathbf{h}}_j \over d \boldsymbol{\theta}^{\mathsf{T}}} &\displaystyle =&\displaystyle \left({\mathbf{1}}_\omega^{\mathsf{T}} \otimes {\mathbf{I}}_s \right) {d \tilde{{\mathbf{B}}}(:,j) \over d \boldsymbol{\theta}^{\mathsf{T}}} {}\vspace{-3pt} \end{array} \end{aligned} $$
(6.46)

Derivation

To derive the sensitivity of the joint distribution of age and stage at death, conditional on some starting age × stage combination, we start by differentiating equation (6.40) for column j of \(\tilde {{\mathbf {B}}}\) and applying the vec operator,
$$\displaystyle \begin{aligned} d \tilde{{\mathbf{B}}}(:,j) = \left( {\mathbf{e}}_j^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) d \mbox{vec} \, \tilde{{\mathbf{B}}}. {}\end{aligned} $$
(6.47)
However, from (6.39), \(\tilde {{\mathbf {B}}} = \tilde {{\mathbf {M}}} \tilde {{\mathbf {N}}}\), so
$$\displaystyle \begin{aligned} d \tilde{{\mathbf{B}}} = \left( d \tilde{{\mathbf{M}}} \right) \tilde{{\mathbf{N}}} + \tilde{{\mathbf{M}}} \left( d \tilde{{\mathbf{N}}} \right).\end{aligned} $$
(6.48)
and
$$\displaystyle \begin{aligned} d \mbox{vec} \, \tilde{{\mathbf{B}}} = \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) d \mbox{vec} \, \tilde{{\mathbf{M}}} + \left( {\mathbf{I}}_{s \omega} \otimes \tilde{{\mathbf{M}}} \right) d \mbox{vec} \, \tilde{{\mathbf{N}}}. {}\end{aligned} $$
(6.49)
The differential of the fundamental matrix \( \tilde {{\mathbf {N}}}\) is
$$\displaystyle \begin{aligned} d \mbox{vec} \, \tilde{{\mathbf{N}}} = \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes \tilde{{\mathbf{N}}} \right) d \mbox{vec} \, \tilde{{\mathbf{U}}}\vspace{-3pt} {} \end{aligned} $$
(6.50)
(Caswell 2006; see Chap.  5). The differential of \(\tilde {{\mathbf {M}}}\) is obtained by rewriting (6.36) as
$$\displaystyle \begin{aligned} \tilde{{\mathbf{M}}} = {\mathbf{I}}_{s \omega} - {\mathbf{I}}_{s \omega} \circ \left( {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \tilde{{\mathbf{U}}} \right),\end{aligned} $$
(6.51)
differentiating,
$$\displaystyle \begin{aligned} d \tilde{{\mathbf{M}}} = - {\mathbf{I}}_{s \omega} \circ \left[ {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \left( d \tilde{{\mathbf{U}}} \right) \right],\end{aligned} $$
(6.52)
and applying the vec operator to obtain
$$\displaystyle \begin{aligned} d \mbox{vec} \, \tilde{{\mathbf{M}}} = - \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_{s \omega} \right) \left( {\mathbf{I}}_{s \omega} \otimes {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \right) d \mbox{vec} \, \tilde{{\mathbf{U}}} {}\end{aligned} $$
(6.53)
Substituting (6.50) and (6.53) into (6.49) gives
$$\displaystyle \begin{aligned} \begin{array}{rcl} d \mbox{vec} \, \tilde{{\mathbf{B}}} &\displaystyle =&\displaystyle \left[ \rule{0in}{2.5ex} - \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_{s \omega} \right) \left( {\mathbf{I}}_{s \omega} \otimes {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \right) \right. \\ &\displaystyle &\displaystyle + \left. \left( {\mathbf{I}}_{s \omega} \otimes \tilde{{\mathbf{M}}} \right) \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes \tilde{{\mathbf{N}}} \right) \rule{0in}{2.5ex} \right] d \mbox{vec} \, \tilde{{\mathbf{U}}}\vspace{-3pt} \end{array} \end{aligned} $$
(6.54)
Substituting this into (6.47) gives
$$\displaystyle \begin{aligned} \begin{array}{rcl} d \tilde{{\mathbf{B}}}(:,j) &\displaystyle =&\displaystyle \left[ \rule{0in}{3.5ex} - \left( {\mathbf{e}}_j^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) \mathcal{D}\, \left( \mbox{vec} \, {\mathbf{I}}_{s \omega} \right) \left( {\mathbf{I}}_{s \omega} \otimes {\mathbf{1}}_{s \omega} {\mathbf{1}}_{s \omega}^{\mathsf{T}} \right) \right. \\ &\displaystyle &\displaystyle \left. \rule{0in}{3.5ex} + \left( {\mathbf{e}}_j^{\mathsf{T}} \otimes {\mathbf{I}}_{s \omega} \right) \left( {\mathbf{I}}_{s \omega} \otimes \tilde{{\mathbf{M}}} \right) \left( \tilde{{\mathbf{N}}}^{\mathsf{T}} \otimes \tilde{{\mathbf{N}}} \right) \right] d \mbox{vec} \, \tilde{{\mathbf{U}}} {} \end{array} \end{aligned} $$
(6.55)
Equation (6.55) can be simplified to obtain (6.44), using the fact that
$$\displaystyle \begin{aligned} \left( \textbf{A} \otimes \textbf{B} \right) \left( \textbf{C} \otimes \textbf{D} \right) = \left( \textbf{A} \textbf{C} \otimes \textbf{B} \textbf{D} \right), \end{aligned}$$
provided the products exist.

Results

Figure 6.3 shows the joint distribution of age and stage at death for a seed of age 1 (one definition of “newborn” in this life cycle), with ω = 40. Almost all seeds will die as seeds, because the germination probability is low, a21 = 0.001; see (6.34). The fates of seedlings (another possible choice for newborn status) are more diverse, and those of juveniles and small adults even moreso; the distributions show what proportion will die as seedlings, juveniles, etc., and at what ages (Fig. 6.3).
Fig. 6.3

The joint probability distribution of age (1, …, 10) and stage (1, …, 7) at death for an individual seed, seedling, juvenile, or small adult of Scotch broom. Stages as in Fig. 6.1

The marginal distribution of age at death, for individuals in each initial stage, is given in Fig. 6.4. Not surprisingly, larger stages have an age distribution of death shifted to later ages, including some probability of survival to age class ω (≥ 40 years in this calculation).
Fig. 6.4

The marginal distributions of age at death for individuals of Scotch broom in each stage. Maximum age is ω = 40. Stages as in Fig. 6.1

The sensitivity of g2 (the marginal distribution of age at death for a seedling) is shown in Fig. 6.5. Changes in the survival of seeds (σ1) have no effect on this distribution, because seedlings have already left the seed stage. Changes in σ2σ7 shift the distribution to progressively older ages, by reducing the probability of death at young ages and increasing it at older ages.
Fig. 6.5

Sensitivity of the marginal distribution of age at death, g2, to the survival probabilities of each stage, for an individual starting in stage 2 (seedlings). Stages as in Fig. 6.1

6.5 Discussion

Models in which individuals are classified by both age and stage extend demographic analyses in several directions. They permit biodemographic analyses of aging to take advantage of the many stage-classified demographic analyses accumulated by ecologists (Salguero-Gómez et al. 2015, 2016). They also permit human demographers to take account of factors other than age in determining mortality, longevity, fertility, and population dynamics.

Age- and stage-specific demographic processes are often combined in demography using multistate life table methods (e.g., Rogers 1975; Willekens 2002, 2014). These are usually focused on cohort dynamics and associated survival statistics (but see Rogers 1975, Chap. 5 for an explicit consideration of population projection). Multistate life table models are written as continuous-parameter, discrete-state Markov chains, where the parameter represents age and the states represent stages. In order to solve the resulting equations, the dynamics must be approximated over a (usually short) finite age interval; this would correspond to the sequence of matrices Ai in the model here. The age × stage-classified model described by \(\tilde {{\mathbf {A}}}\) is a way to solve the discretized equations in a single step, and makes possible a variety of analyses that are difficult or impossible in the usual life table formulation. Further investigation of the relation between continuous multistate life table methods and age × stage-classified models will be interesting.

These analyses blur the distinction (Chap.  5) between implicit and explicit age dependence. If the Ai are truly identical, by definition only implicit age dependence is revealed. But the structure of the age × stage model separates all of the age-dependent Ai, and thus is ready to include any degree of explicit joint dependence of the vital rates on age and stage.

Given sufficient longitudinal data on both age and stage, it is possible to estimate the stage-specific matrices Ai as explicit functions of age; see Peeters et al. (2002) for an example of a study of human heart disease, and Lebreton et al. (2009) for a review of methods used in multistate capture-mark-recapture analysis in ecology. Needless to say, the data requirements for a full age × stage parameterization are challenging. I suspect that the development of estimation methods at intermediate levels of detail will be an important step.

6.5.1 Reducibility and Ergodicity

The properties of \(\tilde {{\mathbf {A}}}\) raise an important theoretical and technical issue regarding population growth, fitness, and selection gradients. The use of λ as a measure of fitness is usually justified by the strong ergodic theorem (Cohen 1979, Caswell 2001, Section 4.5.2), which guarantees the eventual convergence to the stable population structure and growth at a rate given by the dominant eigenvalue λ. A sufficient condition for this convergence is that the projection matrix be irreducible; i.e., that there exist a pathway connecting any two stages. Stott et al. (2010) surveyed published population projection matrices and found that reducible matrices were not uncommon, and explored the implications for ergodicity. Reducible matrices are not as bad as some people think, but it is important to understand their implications, especially for age × stage models.

General results about the irreducibility of block-structured matrices are difficult; see Csetenyi and Logofet (1989), Logofet (1993, Chap. 3), and Logofet and Belova (2007) for some important graph-theoretical results. However, the age × stage matrices developed here are unusual among population models in that they are (almost) always reducible, because they contain categories to which there are no possible pathways. This arises because age 1 individuals are produced only by reproduction. Hence there can never be age 1 individuals in any stage that is not produced by reproduction. For example, Scotch broom reproduces only by seeds, so age 1 seeds appear in the model. However, the matrix \(\tilde {{\mathbf {A}}}\) also contains entries corresponding to age 1 seedlings, age 1 juveniles, age 1 adults, etc. These do not exist, and because there are no pathways to these stages from any other stages, the matrix \(\tilde {{\mathbf {A}}}\) is reducible.

The Perron-Frobenius theorem guarantees that a reducible non-negative matrix will have a real, non-negative, dominant eigenvalue that is at least as large as any of the others. However, the asymptotic population growth rate and structure may depend on initial conditions (Caswell 2001, Section 4.5.4) This means that one must ascertain that the eigenvalues and eigenvectors under analysis correspond to initial conditions of interest.

Appendix A shows that a necessary and sufficient condition for population growth to be described by the dominant eigenvalue λ of \(\tilde {{\mathbf {A}}}\), regardless of the (non-negative and non-zero) initial population vector, is that the left eigenvector v be strictly positive, and that this corresponds to a particular block-triangular form of \(\tilde {{\mathbf {A}}}\). This provides a simple check for the ergodicity of population growth, and justifies the use of λ as a population growth rate and measure of fitness.

Primitivity may be difficult to evaluate for an age × stage matrix (but see Logofet 1993) but as with any projection matrix model, the long-term average growth rate of a primitive matrix is still given by the dominant real eigenvalue.

The matrix \(\tilde {{\mathbf {A}}}\) for Scotch broom in (6.34) is reducible, as shown by calculating \(\left ( {\mathbf {I}}_{s \omega } + \tilde {{\mathbf {A}}} \right )^{s \omega }\) and finding that this matrix contains zeros (Caswell 2001). However, the left eigenvector v is strictly positive, so we know that the population eventually grows at the rate λ regardless of initial conditions.

6.5.2 A Protocol for Age × Stage-Classified Models

The approach outlined here gives a step-by-step procedure for constructing and analyzing age × stage-classified matrix population models.
  1. 1.

    Choose a question, and a corresponding demographic outcome. Are you interested in population dynamics (growth, structure, transients)? Or in cohort dynamics (survival, longevity)? Or in some combination of the two?

     
  2. 2.

    Obtain the stage-classified projection matrices Ai for ages i = 1, …, ω.

     
  3. 3.

    Decompose Ai = Ui + Fi.

     
  4. 4.

    Construct the block-diagonal matrices \(\mathbb {A}\), \(\mathbb {F}\), \(\mathbb {U}\), and \(\mathbb {D}\), according to Eqs. (6.5)–(6.10).

     
  5. 5.

    Construct the age × stage matrices \(\tilde {{\mathbf {A}}}\), \(\tilde {{\mathbf {F}}}\), \(\tilde {{\mathbf {U}}}\) using (6.16) and, if appropriate for the question at hand, also \(\tilde {{\mathbf {M}}}\) and \(\tilde {{\mathbf {P}}}\) using (6.35) and (6.36).

     
  6. 6.

    Analyze the model, e.g., by computing eigenvalues, eigenvectors, the fundamental matrix, etc., as appropriate. If necessary, check for reducibility and ergodicity using the methods in Sect. 6.5.1.

     
  7. 7.
    For sensitivity analysis,
    1. (a)

      choose a dependent variable ξ and a vector of parameters θ,

       
    2. (b)

      compute the sensitivity matrix \(d \boldsymbol {\xi } / d \mbox{vec} \,^{\mathsf {T}} \tilde {{\mathbf {A}}}\),

       
    3. (c)
      compute the matrices:
      $$\displaystyle \begin{aligned} {d \mbox{vec} \, {\mathbf{A}}_i \over d \boldsymbol{\theta}^{\mathsf{T}}}, ~~ {d \mbox{vec} \, {\mathbf{U}}_i \over d \boldsymbol{\theta}^{\mathsf{T}}}, ~~\mbox{and} ~~ {d \mbox{vec} \, {\mathbf{F}}_i \over d \boldsymbol{\theta}^{\mathsf{T}}}\end{aligned} $$
       
    4. (d)

      compute dξdθT according to (6.18).

       
     

The explicit connection between matrix population models and absorbing Markov chain theory makes it possible to analyze both population dynamics and cohort dynamics in a unified framework (cf. Feichtinger 1971a; Caswell 2001, 2006, 2009). Cohort dynamics are, in essence, the demography of individuals. It may seem paradoxical to speak of the demography of individuals, but that is what it is, because the statistical properties of a cohort (e.g., average lifespan) are probabilistic properties of an individual (e.g., life expectancy). Demography in general, and matrix population models in particular, provides the link between the individual and the population.

Footnotes

  1. 1.

    By assuming that F does not depend on σ, I am in effect choosing a pre-breeding census and excluding neonatal mortality from σ.

  2. 2.

    This is the matrix for the Discovery Park population, 1993–1994, edge conditions; taken from the Appendix of Parker (2000).

  3. 3.

    This also leads to a powerful approach, including sensitivity analysis, for cause of death calculations (Caswell and Ouellette 2016, 2018).

  4. 4.

    This holds provided that A is diagonalizable, which is a generic property for linear operators (Hirsch and Smale 1974, p. 157).

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Authors and Affiliations

  • Hal Caswell
    • 1
  1. 1.Biodiversity & Ecosystem DynamicsUniversity of AmsterdamAmsterdamThe Netherlands

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