# Lower Duncan River Kokanee AUC Analysis 2014

The suggested citation for this analytic report is:

*Thorley, J.L. and Hogan, P.M. (2015) Lower Duncan River Kokanee AUC Analysis 2014. URL: https://www.poissonconsulting.ca/f/423435381.*

## Background

Since 2008 aerial surveys have been conducted in the Lower Duncan River (LDR) to count the number of kokanee spawners. The primary objectives of the current analysis report are to:

- Estimate the aerial observer efficiency based on ground counts.
- Estimate the annual kokanee spawner abundance from the aerial counts.
- Estimate the peak spawn timing.

## Methods

### Data Preparation

The data were provided by LGL Limited in the form of an Access database and an Excel spreadsheet.

### Statistical Analysis

Hierarchical Bayesian models were fitted to the data using R version 3.1.2 (Team 2013) and JAGS 3.4.0 (Plummer 2012) which interfaced with each other via jaggernaut 2.2.10 (Thorley 2013). For additional information on hierarchical Bayesian modelling in the BUGS language, of which JAGS uses a dialect, the reader is referred to Kery and Schaub (2011, 41–44).

Unless specified, the models assumed vague (low information) prior distributions (Kery and Schaub 2011, 36). The posterior distributions were estimated from a minimum of 1,000 Markov Chain Monte Carlo (MCMC) samples thinned from the second halves of three chains (Kery and Schaub 2011, 38–40). Model convergence was confirmed by ensuring that Rhat (Kery and Schaub 2011, 40) was less than 1.1 for each of the parameters in the model (Kery and Schaub 2011, 61). Model adequacy was confirmed by examination of residual plots.

The posterior distributions of the *fixed* (Kery and Schaub 2011, 75) parameters are summarised in terms of a *point* estimate (mean), *lower* and *upper* 95% credible limits (2.5th and 97.5th percentiles), the standard deviation (*SD*), percent relative *error* (half the 95% credible interval as a percent of the point estimate) and *significance* (Kery and Schaub 2011, 37, 42).

In general variable selection was achieved by dropping *insignificant* (Kery and Schaub 2011, 37, 42) fixed (Kery and Schaub 2011, 77–82) variables and *uninformative* random variables. A fixed variable was considered to be insignificant if its significance was \(\geq\) 0.05 while a random variable was considered to be uninformative if its percent relative error was \(\geq\) 80%.

The results are displayed graphically by plotting the modelled relationships between particular variables and the response with 95% credible intervals (CRIs) with the remaining variables held constant. In general, continuous and discrete fixed variables are held constant at their mean and first level values respectively while random variables are held constant at their typical values (expected values of the underlying hyperdistributions) (Kery and Schaub 2011, 77–82). Where informative the influence of particular variables is expressed in terms of the *effect size* (i.e., percent change in the response variable) with 95% CRIs (Bradford, Korman, and Higgins 2005).

### Observer Efficiency

The aerial observer efficiency was estimated from ground counts using a Poisson model. Key assumptions of the observer efficiency model include:

- The spawner abundance at a site does not change between the ground and aerial count.
- The ground observers are unbiased with the ground count being drawn from a Poisson distribution.
- The aerial observer efficiency does not vary systematically with abundance or channel type, i.e., sidechannel versus main channel.
- The aerial counts are drawn from an overdispersed Poisson distribution.

### Area-Under-the-Curve

The aerial spawner counts were analysed using a hierarchical Bayesian Area-Under-the-Curve (AUC) model (Hilborn, Bue, and Sharr 1999). Key assumptions of the AUC model include:

- Spawner arrival and departure are normally distributed (Hilborn, Bue, and Sharr 1999)
- The duration of spawning is constant across years
- The peak spawn timing in each year is drawn from a normal distribution (Su, Adkison, and Van Alen 2001)
- The residence time is between 7 and 14 days for spawners (Acara 1970, @morbey_timing_2003)
- The observer efficiency is described by a normal distribution with a mean of 1.05 and SD of 0.15 and lower and upper limits of 0.79 and 1.36 as estimated by the observer efficiency model
- The residual variation in the spawner counts is normally distributed

### Model Code

The JAGS model code, which uses a series of naming conventions, is presented below.

#### Observer Efficiency

Variable/Parameter | Description |
---|---|

`Aerial[i]` |
Aerial count for `i` ^{th} survey |

`bAbundance` |
`log(eAbundance)` intercept |

`bEfficiency` |
`eEfficiency` intercept |

`eAbundance[i]` |
Expected spawner abundance for `i` ^{th} survey |

`eAerial[i]` |
Expected aerial count for `i` ^{th} survey |

`eEfficiency[i]` |
Expected aerial observer efficiency for `i` ^{th} survey |

`Ground[i]` |
Ground count for `i` ^{th} survey |

`sAbundance` |
SD of residual variation in `log(eAbundance)` |

`sDispersion` |
SD of overdispersion |

##### Observer Efficiency - Model1

```
model {
bEfficiency ~ dunif(0, 3)
bAbundance ~ dnorm(5, 5^-2)
sAbundance ~ dunif(0, 5)
sDispersion ~ dunif(0, 5)
for (i in 1:length(Aerial)) {
eEfficiency[i] <- bEfficiency
eAbundance[i] ~ dlnorm(bAbundance, sAbundance^-2)
Ground[i] ~ dpois(eAbundance[i])
eAerial[i] <- eAbundance[i] * eEfficiency[i]
eDispersion[i] ~ dgamma(1 / sDispersion^2, 1 / sDispersion^2)
Aerial[i] ~ dpois(eAerial[i] * eDispersion[i])
}
}
```

#### Area-Under-The-Curve

Variable/Parameter | Description |
---|---|

`bAbundance` |
`log(eAbundance)` intercept |

`bAbundanceYear[i]` |
Effect of `i` ^{th} year on `log(eAbundance)` |

`bDuration` |
`eDuration` intercept |

`bEfficiency` |
`eEfficiency` intercept |

`bPeakTiming` |
`ePeakTiming` intercept |

`bPeakTimingYear[i]` |
Effect of `i` ^{th} year on `ePeakTiming` |

`bResidenceTime` |
Spawner residence time |

`Count[i]` |
Spawner count for `i` ^{th} survey |

`Dayte[i]` |
Centred day of the year for `i` ^{th} survey |

`eAbundance[i]` |
Expected annual spawner abundance for `i` ^{th} survey |

`eCount[i]` |
Expected spawner count for `i` ^{th} survey |

`eDuration[i]` |
Expected SD of the duration of spawner arrival timing |

`eEfficiency[i]` |
Expected aerial observer efficiency for `i` ^{th} survey |

`ePeakTiming[i]` |
Expected timing of annual peak spawner abundance for `i` ^{th} survey |

`eSpawners[i]` |
Expected number of spawners for `i` ^{th} survey |

`sAbundanceYear` |
SD of effect of year on `log(eAbundance)` |

`sCount` |
SD of residual variation in `eCount` |

`sPeakTimingYear` |
SD of effect of year on `ePeakTiming` |

##### Area-Under-The-Curve - Model1

```
model {
bEfficiency ~ dnorm(1.05, 0.15^-2) T(0.79, 1.36)
bAbundance ~ dnorm(10, 5^-2)
bPeakTiming ~ dnorm(0, 5)
bDuration ~ dunif(0, 42)
sAbundanceYear ~ dunif(0, 5)
sPeakTimingYear ~ dunif(0, 28)
for (i in 1:nYear) {
bAbundanceYear[i] ~ dnorm (0, sAbundanceYear^-2)
bPeakTimingYear[i] ~ dnorm (0, sPeakTimingYear^-2)
}
bResidenceTime ~ dunif(7, 14)
sCount ~ dunif(0, 10000)
for (i in 1:length(Count)) {
log(eAbundance[i]) <- bAbundance
+ bAbundanceYear[Year[i]]
ePeakTiming[i] <- bPeakTiming
+ bPeakTimingYear[Year[i]]
eDuration[i] <- bDuration
eSpawners[i] <- (phi((Dayte[i] - (ePeakTiming[i] - bResidenceTime/2))
/ eDuration[i])
- phi((Dayte[i] - (ePeakTiming[i] + bResidenceTime/2))
/ eDuration[i]))
* eAbundance[i]
eEfficiency[i] <- bEfficiency
eCount[i] <- eSpawners[i] * eEfficiency[i]
Count[i] ~ dnorm(eCount[i], sCount^-2)
}
}
```

## Results

### Model Parameters

The posterior distributions for the *fixed* (Kery and Schaub 2011 p. 75) parameters in each model are summarised below.

#### Observer Efficiency

Parameter | Estimate | Lower | Upper | SD | Error | Significance |
---|---|---|---|---|---|---|

bAbundance | 4.8360 | 3.6790 | 5.9820 | 0.5930 | 24 | 0.001 |

bEfficiency | 1.0483 | 0.8304 | 1.3185 | 0.1227 | 23 | 0.001 |

sAbundance | 1.9800 | 1.2640 | 3.2830 | 0.5180 | 51 | 0.001 |

sDispersion | 0.5353 | 0.3389 | 0.8234 | 0.1250 | 45 | 0.001 |

Convergence | Iterations |
---|---|

1.02 | 10000 |

#### Area-Under-The-Curve

Parameter | Estimate | Lower | Upper | SD | Error | Significance |
---|---|---|---|---|---|---|

bAbundance | 10.2220 | 9.4060 | 11.0260 | 0.399 | 8 | 0.0010 |

bDuration | 5.6230 | 1.7600 | 7.3690 | 1.261 | 50 | 0.0010 |

bEfficiency | 1.0632 | 0.7882 | 1.3756 | 0.153 | 28 | 0.0010 |

bPeakTiming | 0.1660 | -0.7370 | 1.0320 | 0.449 | 530 | 0.6867 |

bResidenceTime | 10.8580 | 7.1770 | 13.8700 | 2.157 | 31 | 0.0010 |

sAbundanceYear | 0.8470 | 0.4080 | 1.7760 | 0.352 | 81 | 0.0010 |

sCount | 5407.0000 | 4536.0000 | 6450.0000 | 492.000 | 18 | 0.0010 |

sPeakTimingYear | 9.9500 | 5.1300 | 18.6000 | 3.540 | 68 | 0.0010 |

Convergence | Iterations |
---|---|

1.04 | 10000 |

### Figures

#### Observer Efficiency

#### Area-Under-The-Curve

## Acknowledgements

The organisations and individuals whose contributions have made this analysis report possible include:

- BC Hydro
- Guy Martel

- Okanagan National Alliance
- Michael Zimmer
- Natasha Audy
- Skyeler Folks

- LGL Limited
- Elmar Plate

- Amec Earth and Environmental
- Louise Porto
- Crystal Lawrence
- Clint Tarala

- Poisson Consulting Ltd.
- Robyn Irvine

## References

Acara, A. H. 1970. “The Meadow Creek Spawning Channel. Unpublished Report.” Victoria, BC: Fish; Wildlife Branch.

Bradford, Michael J, Josh Korman, and Paul S Higgins. 2005. “Using Confidence Intervals to Estimate the Response of Salmon Populations (Oncorhynchus Spp.) to Experimental Habitat Alterations.” *Canadian Journal of Fisheries and Aquatic Sciences* 62 (12): 2716–26. https://doi.org/10.1139/f05-179.

Hilborn, Ray, Brian G Bue, and Samuel Sharr. 1999. “Estimating Spawning Escapements from Periodic Counts: A Comparison of Methods.” *Canadian Journal of Fisheries and Aquatic Sciences* 56 (5): 888–96. https://doi.org/10.1139/f99-013.

Kery, Marc, and Michael Schaub. 2011. *Bayesian Population Analysis Using WinBUGS : A Hierarchical Perspective*. Boston: Academic Press. http://www.vogelwarte.ch/bpa.html.

Morbey, Y. E., and R. C. Ydenberg. 2003. “Timing Games in the Reproductive Phenology of Female Pacific Salmon (Oncorhynchus Spp.).” *The American Naturalist* 161 (2): 284–98. http://www.jstor.org/stable/10.1086/345785.

Plummer, Martyn. 2012. “JAGS Version 3.3.0 User Manual.” http://sourceforge.net/projects/mcmc-jags/files/Manuals/3.x/.

Su, Zhenming, Milo D. Adkison, and Benjamin W. Van Alen. 2001. “A Hierarchical Bayesian Model for Estimating Historical Salmon Escapement and Escapement Timing.” *Canadian Journal of Fisheries and Aquatic Sciences* 58 (8): 1648–62. https://doi.org/10.1139/cjfas-58-8-1648.

Team, R Core. 2013. “R: A Language and Environment for Statistical Computing.” Vienna, Austria: R Foundation for Statistical Computing. http://www.R-project.org.

Thorley, J. L. 2013. “Jaggernaut: An R Package to Facilitate Bayesian Analyses Using JAGS (Just Another Gibbs Sampler).” Nelson, B.C.: Poisson Consulting Ltd. https://github.com/poissonconsulting/jaggernaut.