Appendix A Population response to a localized disturbance Basic model Assume a single, time-invariant, disturbance at location xd , with all model parameters having constant values elsewhere. At equilibrium, Eq. Error! Reference source not found. in the text implies that for all x xd , 0 e N *( x) R e0 N *( x) m N *( x) 0 t LD x x y dy . LD N ( y) exp * 0 (A.1) Differentiating Eq. (A.1) with respect to x yields 0 e0 m x dN * x e0 * e x y N x 20 exp N * y exp dy . dx LD L LD D0 LD From Eq. (A.1), the final term (identified by the bracket) is equal to (A.2) R e0 m N * x . LD Making this substitution, defining and substituting N * x N H* 1 n x , and re-arranging (A.2) yields the differential equation dn x 1 n x dx LR (A.3) where N H* Rm 1 is the spatially homogeneous steady state (discussed in the text) and e e LR LD 1 0 LD 0 if e0 m . m m ( .4) Thus, downstream of any disturbance, the equilibrium population density approaches its spatially homogeneous value exponentially with a decay constant 1/LR. Model with general one-sided dispersal kernel An extension of the above argument shows that the approximate result in Eq. ( .4) holds for any one-sided kernel h(u) in Eq. (1), provided h(u ) 0 at least exponentially as u (i.e., we exclude some “fat-tailed” kernels). The model assumes zero mortality in transit, implying h(u)du 1 , and the assumption on the tail guarantees that the mean distance traveled per jump 0 is LD uh(u )du . Linearizing Eq. Error! Reference source not found. about the spatially 0 homogeneous steady state (see Chapter 5, Nisbet and Gurney 2003) yields the linear equation x 0 e0n( x) mn( x) e0 h( x y)n( y )dy . ( .5) 0 With the general kernel, the decay in population density downstream of a disturbance is no longer a pure exponential, but can be represented as a sum or integral of decaying exponential terms, each of which is a solution of Eq. ( .5). If a typical term is n( x) exp sx , then we define the response length to be the reciprocal of the smallest real value of s for which the exponential form is a solution. Substituting s LR 1 , inserting the exponential solution in Eq. ( .5), and rearranging terms, shows that LR is obtained by solving the equation x u e0 m h(u ) exp du . e0 LR 0 We approximate Eq. ( .6) by replacing the upper limit in the integral by infinity and setting exp su 1 su . Then, Eq. ( .6) implies ( .6) e0 m L k (u ) 1 su du 1 sLD 1 D . e0 LR 0 From this it follows that LR LD ( .7) e0 , which is the desired result. m Density dependence Suppose R, m, and e0 are functions of local density. Then, Eq. (A.1) is replaced by x x y 1 0 R N ( x) m N ( x) e0 N ( x) N ( x) e0 N * ( y ) N * ( y ) exp dy LD 0 LD * * * * ( .8) Recall that the spatially homogeneous equilibrium is denoted by N H* . We use R , e0 , and m to denote the spatial mean value of the recruitment rate, the per capita emigration rate, and the mortality rate, respectively. Finally, we define de dR dm RN* , e*N 0 , m*N . dN N N H * dN N N H * dN N N H * ( .9) Linearizing Eq. ( .8) about the spatially homogenous equilibrium yields the following equation for n(x) (defined above in Eq. (A.3)): 0 RN* m N H* m*N e0 N H* e*N n x 1 LD x e 0 0 x y N H* e*N n y exp dy . LD ( .10) This equation is similar in form to Eq. (A.1) and the response length can be calculated by the same reasoning as was used for that equation, yielding the result e0 N H* e*N LR LD 1 * * * m N H mH RH . ( .11) Appendix B Equilibrium population responses to spatial environmental variability in parameters describing demography As in the text, consider first variation in the recruitment rate alone. At equilibrium, Eq. (1) takes the form 0 e N *( x) R( x) e0 N *( x) m N *( x) 0 t LD x x y dy . LD N ( y) exp * 0 (B.1) By differentiating this equation with respect to x, and then proceeding as in appendix A, it can be shown that the equilibrium population density obeys the differential equation dN x 1 1 dR x N x R x . LD dx LR mLR dx (B.2) The structure of solution to an equation of this form is the sum of two components (details in Nisbet & Gurney 2003, pp 27-29) – a “complementary function” involving the initial condition (x = 0), and a “particular integral” solution that is independent of the initial conditions and represents the persisting response, i.e. the spatial variation far from x = 0. Here we are only concerned with the particular integral. With the sinusoidal form of variation in recruitment assumed in Eq. Error! Reference source not found., there are two “brute force” ways of deriving the solution (see Nisbet & Gurney 2003, pp 29-39). The first option exploits the fact that the particular integral is unique; we assume the solution has the form given in Eq. Error! Reference source not found. and with some tedious trigonometry show that it is indeed a solution if Eq. Error! Reference source not found. is valid. The second (mathematically equivalent) option is to perform the analogous calculation using complex exponentials. The most general approach, applicable to arbitrary spatial variation and not just sinusoids, is to use Fourier analysis (for an ecologically oriented introduction, see Nisbet & Gurney 2003). The spatial distribution of recruitment and the resulting equilibrium population distribution are expressed as a sum or integral of sinusoids with different spatial frequencies, k: 1 R( x) 2 R(k ) exp ikx dk and 1 N ( x) 2 N (k ) exp ikx dk . (B.3) The spatial frequency k is related to the more easily interpreted spatial wavelength LE used in the text by the relationship k 2 LE . The functions R(k ) and N (k ) are the Fourier transforms of R(x) and N(x) over the spatial domain 0 x , and are defined by 0 0 R k R x exp ikx dx and N k N x exp ikx dx . (B.4) The Fourier transform can be interpreted as a complex number whose modulus represents the amplitude and whose argument represents the phase of a sinusoidal pattern of environmental variability. The motivation for its use in the our work is that, although the spatial distributions of recruitment and of the population are related by a differential equation, their Fourier transforms are related by an algebraic equation that can be readily interpreted. If R and N H* denote the spatial means of R(x) and N(x) respectively, we can write the relation between the Fourier transforms of R(x) and N(x) in the form N (k ) R(k ) . TR (k ) * NH R (B.5) In Eq. (B.5), the transfer function TR(k) is a complex function whose modulus represents the ratio of the proportional amplitudes of sinusoids of spatial frequency k; this is the ratio “b/a” used in the text. By Fourier transforming Eq. (B.2), it can be shown with a little algebra – and noting that the transform of the derivative of a function is ik times the transform of the function (Nisbet & Gurney 2003, Appendix F) – that TR k with modulus 1 LD ik , 1 LR ik (B.6) k LR LD 1 L2D k 2 and argument tan 1 . The expression for b/a in Eq. 2 2 2 1 LR k 1 LD LR k Error! Reference source not found. of the text follows immediately from the modulus (noting that k 2 LE ). The argument represents the phase shift (i.e. displacement in space of the peaks or troughs, expressed in radians) between the sinusoidal variations in recruitment and in the population. The downstream displacement LL is obtained by multiplying this lag by LE 2 . Analogous analyses can be performed to describe equilibrium population responses to spatial variation in the per capita mortality rate m(x), but one new complication occurs. In this case, Eq. (B.1) is replaced by x y 1 N *( x) R e0 N *( x) m( x) N *( x) e0 N *( y ) exp dy . t LD LD 0 x 0 (B.7) One term in this equation (indicated by the underbrace) involves a product that impedes progress to a simple algebraic formula like Eq. (B.5). To avoid this problem, we linearize Eq. (B.7) about the spatial mean values of the per capita mortality rate and the population density (for examples of such linearization, see Chapter 5 of Nisbet & Gurney 2003). If we define small deviations of the per capita mortality rate from its mean value as m( x) m 1 ( x) and the resulting population fluctuations as N * ( x) N H* 1 n( x) , then by substituting these definitions and Fourier transforming the linearized form of Eq. (B.7) and rearranging terms, we find that the transfer function for mortality fluctuations is Tm (k ) 1 LD ik n( k ) , (k ) 1 LR ik (B.8) which is identical to Eq. (B.6), apart from the negative sign that arises because a uniform (k = 0) increase in m causes a decrease in population density. Appendix C Equilibrium population responses to spatial environmental variability in parameters describing dispersal Eq. Error! Reference source not found. in the text can be derived as a limiting situation for a more general model that uses a pair of coupled partial differential equations that separately describe dispersing ND(x) and sessile N(x) sub-populations (Lutscher et al. 2005). At steady state, these equations take the form 0 0 N * x t N D* x t R x m x e0 x N * x N D* x v x v x N D* x N D* x x N D* x e0 x N * x x x (C.1) where v is the advection speed, μ is the rate of settlement from the dispersal to the sessile mode, and the average dispersal length LD equals v . Equation Error! Reference source not found. is obtained as the limiting case where and v but the ratio v retains a fixed finite value LD. This corresponds to a situation where organisms spend an infinitesimally small portion of their lifetime in transit between locations on the benthos. Mathematically, the limit is problematic if v and/or μ vary spatially, so in this appendix we work with the system in Eq. (C.1) , taking any required limits at the end of calculations. Consider small deviations from spatial population averages defined by N * x N 1 n x and N D* x N D 1 nD x (C.2) caused by one or more of the parameters varying spatially, e0 x e0 1 x ; x 1 x ; v x v 1 x . Linearizing Eq. (C.1) yields (C.3) 0 e0 N n x x mNn x N D nD x x n 0 v N D D N D nD x x e0 N n x x . x x (C.4) By taking Fourier transforms and rearranging terms, we can derive a transfer function that relates variation in the per capita emigration rate to variation in the population distribution of sessile individuals (assuming ( x) 0 and ( x) 0 ), T (k ) e LD ik ( L LD )ik n( k ) 0 R . (k ) m 1 LR ik 1 LR ik (C.5) The proportional amplitude ratio, plotted in Fig 3d, is T (k ) LD k 2 ( LR LD ) b e0 . 2 2 a m 1 k LR LE 2 4 2 LR 2 (C.6) L The downstream displacement is tan 1 E . If we follow the conventional rule that the 2 LR (multi-valued) inverse tangent function is assigned a value in the range / 2, / 2 , this would imply an ecologically impossible upstream displacement of an effect from its cause. The downstream displacement LL is obtained by adding one wavelength with the result that LL LE L LE tan 1 E . This formula was used to calculate Fig. 3e. 2 2 LR There are two components of LD that may vary spatially: the settlement rate μ, and the advection speed v. Equation (C.4) can be used to derive the transfer function for both sources of variation. Both transfer functions are to proportional to N D , which implies T k 0 as N D 0 . Appendix D Additional background on parameter estimation for Leuctra nigra in Broadstone Stream Broadstone Stream lacks fish, thus we assume that L. nigra mortality is due entirely to predation by the two common predators in this stream, the caddisfly Plectrocnemia conspersa and the alderfly Sialis fuliginosa. Speirs et al. (2000) reported that P. conspersa had an average density of 119 m-2 and an attack rate on L. nigra of 2.77 x 10-5 m2 day-1. S. fuliginosa has an average reported density of 44 m-2 and an attack rate while foraging on L. nigra of 1.92 x 10-5 m2 day-1. Assuming an additive effect of both predators on L. nigra mortality and constant predator densities, we obtain an L. nigra mortality rate m = 0.00414 day-1. Winterbottom et al. (1997b) present the ratio of the density of colonists that settled in a cleared experimental area over one week to background benthic densities (their “Index of Mobility”) across a range of daily discharges D. Assuming the surrounding system was in equilibrium (i.e., immigration and emigration in the surrounding habitat were in balance), but that no organisms left the experimental arena (in which case immigration rate can be estimated from the number of organisms accumulated in the experimental area), the Index of Mobility provides a per capita emigration rate in units of week-1. Winterbottom et al.’s data suggest an exponential relationship, e0 eB 0 exp D , (D.1) yielding a baseline per capita emigration value of eB0 = 0.98 week-1, which equals 0.14 d-1, and η = 71.55 seconds m-3. Speirs & Gurney (2001) report that the average cross-sectional area of Broadstone Stream is 0.1932 m2. Recasting η as responsiveness to velocity Vs (in m s-1), rather than discharge, yields η = 13.82 seconds m-1. Elliott (1971) observed that the dispersal kernel for L. nigra was well-described by an exponential distribution, which was approximately directly proportional to stream velocity at LD 35 VS , where VS is the stream velocity in m s-1 and LD is the average dispersal length in meters. (D.2)