Research article 25 Jan 2019
Research article  25 Jan 2019
The selection of directional sectors for the analysis of extreme wind speed
 ^{1}Group of Environmental Fluid Dynamics, Andalusian Institute for Earth System Research (IISTA), University of Granada, Avda. del Mediterráneo, s/n, 18006, Granada, Spain
 ^{2}Instituto de Mecánica de los Fluidos e Ingeniería Ambiental, Universidad de la República, Julio Herrera y Reissig 565, 11300 Montevideo, Uruguay
 ^{1}Group of Environmental Fluid Dynamics, Andalusian Institute for Earth System Research (IISTA), University of Granada, Avda. del Mediterráneo, s/n, 18006, Granada, Spain
 ^{2}Instituto de Mecánica de los Fluidos e Ingeniería Ambiental, Universidad de la República, Julio Herrera y Reissig 565, 11300 Montevideo, Uruguay
Correspondence: Pedro Folgueras (folgueras@ugr.es)
Hide author detailsCorrespondence: Pedro Folgueras (folgueras@ugr.es)
This paper presents a rational method for the selection of the most suitable directional sectors in the analysis of extreme wind loads on structures. It takes into consideration the main sources of uncertainty stemming from sector selection and leads to the definition of independent and statistically homogeneous directional sectors.
This method is applied to the selection of directional sectors for the calculation of the design wind speed of a structure located at the mouth of the Río de la Plata. The results in the estimated reliability and costs were compared to those obtained with conventional engineering methods, revealing significant differences. It was found that the proposed method is a simple and objective tool for the selection of directional sectors, which comply with the working hypothesis of the directional models, and offers better guarantees for dimensioning than the use of more traditional engineering approaches for sectorial division.
Wind directionality effects have a well recognized impact on the characteristics of the extreme wind loads of structures. The methods for dealing with it usually involve the division of available data into sectors (whose statistical behavior is assumed to be homogeneous) and the evaluation of the extreme behavior of the wind velocity in each of them. The implicit decisions involved in this procedure (and its uncertainty) include (i) the identification of extreme values, (ii) the selection of the optimal model for data fitting, (iii) the definition of the directional sectors for calculation, and (iv) the characterization of the dependence among directional extremes. From all of them, the selection of the sectors, which is the subject of this article, has received the least attention.
Wind tunnel laboratories and building codes have developed multiple methods in order to consider the influence of directionality on the estimation of extreme wind speeds and windinduced quantities, such as the “upcrossing” method, the “worst case” method, the “storm passage” method, etc. (see, for example, Irwin et al., 2005; Isyumov et al., 2014). Among them, the “sectorbysector” approaches attempt to produce directional wind speeds, or directional wind speed multipliers, for a discrete number of defined wind directions. The model of extreme values is fit in each sector separately assuming data allocated in sectors are independent. When the directional wind speeds are combined with the measured structural response coefficients, the largest resulting response from any direction is deemed to be an appropriate design value (Holmes, 2015).
Recently, Zhang and Chen (2015, 2016) proposed a methodology to estimate the probability distribution of the load responses of structures under extreme wind conditions, which is an extension of the probabilistic methods of Cook and Mayne (1979, 1980). This method allows the study of both the directional extreme winds and the directional distribution of the response coefficients, separately. If the directional response coefficients are poorly correlated and if they can be estimated from wind tunnel tests for a particular structure, then the main challenge in applying the method is the calculation of the multivariate distribution of the extreme wind directional velocity.
Using a priori defined divisions to this end results, in general, in correlated directional sectors. This complicates the use of these methods since the dependence structure among the extreme directional values of wind speeds must be modeled using any of the existing approaches (e.g., Simiu et al., 1985; Coles and Walshaw, 1994; Solari and Losada, 2016). It also poses other potential issues such as the lack of enough data in some sectors or the existence of nonhomogeneous populations, among others. Nevertheless, engineering methods generally opt for the use of simple criteria, mainly based on the definition of sectors of fixed amplitude, oriented according to the cardinal directions (see, e.g., Mayne, 1979; Cook, 1982, 1983; Cook and Miller, 1999, which use 30^{∘} sectors). Also, current regulations and guidelines (API, 2000; DNV, 2010; ISO, 2005) for the design of offshore structures (which consider wind directionality but also other directional climatic agents, such as waves and currents) deal with the division of the compass into sectors. The API (API, 2000) recommendations suggest taking the main direction of the agent as the reference direction whereas the DNV (DNV, 2010) leaves this decision to the engineer. As an alternative to these approaches, ISO (2005) proposes the use of naturally defined sectors based on the directionality inherent in the data measured or obtained in reanalysis. However, this guideline does not provide any specific criteria that can be used to implement this approach.
In this work an alternative methodology that defines the distribution of the extreme wind directional velocity in a nonarbitrary manner is proposed. Both intrasectorial homogeneity and intersectorial independence conditions are imposed, among others, to obtain the directional sectors. Unlike previous approaches, this methodology results in uncorrelated sectors, so it is not necessary to use dependence models (e.g., copulas) and allows the approximation of the multivariate (directional) extreme distribution simply as the product of the marginals. In addition, this method assures directional sectors that contain data in consonance with the working hypotheses of the directional model for the extremes.
This methodology was applied to the study of extreme values of wind speed at the study zone of the mouth of the Río de la Plata, where directional effects are of particular importance. The effect of directional sector selection on the design wind speed of a structure was also estimated. These calculations and their consequences for project design reliability were compared with the results obtained with traditional engineering methods based on the use of divisions with equal size sectors and a northern direction of origin.
The rest of this paper is organized as follows. After defining the research problem, Sect. 2 delimits the framework and specifies the main sources of uncertainty considered. The methodology for the selection of directional sectors is then explained. The case study in Sect. 3 describes the wind characteristics in the study zone, followed by the quantification of the impact of sector selection, based on indicators for each source of uncertainty. These results are compared to those obtained with conventional engineering methods. In Sect. 4, a simple example is used for illustrating the potential consequences of the selection of directional sectors for project design reliability. Finally, Sect. 5 presents the main conclusions that can be derived from this research.
2.1 Problem statement
The selection of calculation sectors affects the estimates of directional extreme values, which may impact the evaluation of project costs and structural reliability. The main factors that influence the result are the following: (1) the procedure followed to identify the extreme events of the sector samples, (2) the validity of the model used to characterize extreme behavior, (3) the goodness of parameter estimation, (4) the capacity of each model to represent extreme behavior in the total amplitude of the corresponding sector, and (5) the validity of the dependence model among extreme values in different sectors. All of these factors are in turn conditioned by the quantity of available data and their directional distribution.
For the selection of calculation sectors, this paper describes a procedure that considers the main sources of uncertainty stemming from the choice of sectors. Firstly, the candidate divisions are limited to those whose sectors are compatible with the selected model of extreme values and which have a given minimum quantity of information. Secondly, the consequences of this selection are evaluated for each division by means of indicators that characterize the intrasectorial homogeneity of the samples, the uncertainty of the estimates of directional extreme values, and their intersectorial independence. Finally, the division with the best overall behavior is selected, based on the set of indicators. This methodology is outlined in the flowchart in Fig. 1.
2.1.1 Requirements for the preselection of candidate division
Extreme events are isolated in each sector for different possible angular divisions by means of any appropriate technique, such as peaks over threshold (POT), block maxima (Coles, 2001), weather patterns (Solari and Alonso, 2017), etc. Divisions containing sectors that do not meet the following two requirements are excluded: (1) the division must have the quantity of data minimally necessary to test the validity of the models used for describing the extreme behavior; (2) the data in each division must also be compatible with these models.
Regarding the first requirement, the minimum acceptable quantity of data in each sector (or semisector) should be such that the probability of a Type II error (a false negative finding) in the statistical hypothesis tests that are used in the proposed method is less than a given value β. For this purpose, the power curves of these tests, which relate β to the minimum number of data, are used. The significance level α and the effect size of these curves should be defined in consonance with the problem under study. Regarding the second requirement, the extreme events should not be incompatible with the selected model of extreme values. Compliance with this requirement is evaluated by means of bilateral hypothesis testing, e.g., Anderson–Darling (Anderson and Darling, 1952) or Kolmogorov–Smirnov (KS) (Kolmogoroff, 1941; Smirnoff, 1939), with significance level α.
2.1.2 Selection of the calculation sectors
The next step involves the evaluation of the consequences of sector selection on (i) the intrasectorial homogeneity of the samples, (ii) the uncertainty of the estimates of directional values, and (iii) their intersectorial independence. To this end, the use of three indicators based on standard statistical analysis and which are measured on a 0–1 scale is proposed. This approach is also compatible with the use of other indicators specific to the problem under consideration.
The first indicator characterizes the variability in the statistical behavior of extreme events along the arc of each sector. Significant discrepancies among the subsamples of a sector can indicate the presence of different populations, which is incompatible with the hypotheses of the model used. The second indicator reflects the uncertainty of the fit of extreme values by analyzing their asymptotic distribution. Finally, the third indicator evaluates the incompatibility of the sectors with the independence among sectorial extreme values. This independence occurs when each storm event is restricted to one sector and does not move to neighboring ones.
The division selected is the one that shows the best overall performance as reflected in the set of characteristics evaluated by the indicators. This leads to the creation of a new global indicator, which is a function of the other three and which allows for sorting the candidate divisions according to the selected criterion.
2.2 Specification of indicators
2.2.1 Indicator of intrasectorial homogeneity
In order to compare the statistical homogeneity of extreme values in different regions of the same sector, the sector is divided into two subsectors of equal amplitude (S_{1} and S_{2}). A generalized KS (Smirnoff, 1939; Kolmogoroff, 1941) test is performed, which evaluates the degree of incompatibility of the two subsamples of POT events in virtue of the null hypothesis that both belong to the same population.
As an indicator of this characteristic in a sector, the p value of the contrast is used. This indicates the probability, given the null hypothesis H_{0} is true, that the KS test statistic, D, has a value that is greater than or equal to that given by the data. The smaller the p value, the grater the statistical incompatibility of the data with the null hypothesis, if the underlaying assumption used to calculate the p values holds (Wasserstein and Lazar, 2016). The behavior of the sectors is evaluated by means of the geometric mean given by Eq. (1), where d_{m} is the test statistic in each sector.
2.2.2 Indicator of uncertainty of the estimators
This indicator gives a measure of the uncertainty stemming from the choice of sectors, in the estimations of extreme values. This uncertainty is characterized by analyzing the asymptotic distribution of the extreme values within the context of delta method hypotheses (e.g., Coles, 2001). For this purpose, in each sector, the probability corresponding to the intervals defined by means of the estimated extreme value and a discrepancy ±ε_{0} is evaluated. The performance of the set of sectors is calculated by means of the geometric mean of the results obtained for each one, as shown in Eq. (2).
where ${\mathrm{\Phi}}_{\mathrm{0},\mathrm{1}}(\cdot )$ is the value of the standard normal distribution function, σ_{E} is the standard deviation of the estimator, and the discrepancy ε_{0} (%) is a parameter that must be previously defined.
2.2.3 Indicator of intersectorial independence
In the case of completely independent sectors, the following relation is verified:
where Y is the annual maximum value of omnidirectional variables, and X_{m} is the annual maximum value of directional variables in sector m.
The p value of the KS test (Smirnoff, 1939; Kolmogoroff, 1941) is used as an indicator of the incompatibility of the omnidirectional data with a model based on the independence of sectorial extremes corresponding to a given division (Eq. 3). The null hypothesis H_{0} is thus assumed according to which omnidirectional annual maximum values conform to this model. The sample of omnidirectional annual maximums is checked against the distribution obtained by multiplying directional distributions that are fit to the data. The value of the indicator, $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{3}}}$, is given by Eq. (4), where d is the test statistic, corresponding to the sample of omnidirectional annual maximums.
2.2.4 Global indicator
In order to consider the previous indicators as a whole, the expression in Eq. (5) was used,
where $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{1}}}$, $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{2}}}$, and $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{3}}}$ are the indicators of the intrasectorial maximum homogeneity, minimum uncertainty in estimations, and intersectorial maximum independence, respectively. All the indicators are measured on the same scale 0–1, where 0 represents the worst qualities and 1 the best.
2.3 Outline of the procedure
The procedure involves the following steps:

identification of extreme events per sector;

definition of requirements and conditioning factors (Sect. 2.1.1)
 a.
requirements regarding data quantity,
 b.
requirements for the validity of the models by sector;
 a.

preselection of the sets of sectors that meet these requirements;

selection of the calculation sectors (Sect. 2.1.2);
 a.
evaluation of the indicators in each candidate division (Sect. 2.2);
 b.
selection of the set of sectors with the best overall indicator value.
 a.
3.1 Description of the wind at the site
The study site is located in front of the mouth of the Río de la Plata (36^{∘} S, 55^{∘} W) on the east coast of South America between Uruguay and Argentina (Fig. 2). The estuary there is one of the largest in the world and is of great interest from both a social and ecological perspective. Since it is also an extremely active zone of cyclogenesis, it has been the focus of much research (e.g., Framiñan et al., 1999; Guerrero et al., 1997; Solari and Losada, 2016).
Atmospheric circulation in the area is controlled by the South Atlantic highpressure system, which brings hot, humid air to the estuary. In addition, coldair systems from this anticyclone bring masses of cold air to the zone approximately every 4 days. This means that wind direction frequently varies since northeasterly winds alternate with southeasterly winds every few days (Simionato et al., 2007).
Furthermore, intense storms, known as sudestadas (southeast blows), often occur during the summer. These events are produced by anticyclonic cells from subtropical latitudes with strong southeasterly winds, loaded with humidity, which bring heavy rain to the estuary. The river's southeast alignment produces rough seas and meteorological tides. During the winter months, masses of cold air from the Antarctic anticyclone (pamperos) blow from the southeast, causing a considerable drop in temperatures.
3.2 Directional variability in extreme events
The research data used in this study come from reanalysis time series of the ERAInterim program (Dee et al., 2011), belonging to the European Centre for MediumRange Weather Forecasts (ECMWF). The variables extracted from the database are 10 min average wind speed components U and V at a height of 10 m and recorded at a rate of 6 h. There were 37 years of data available from January 1979 until December 2015. The characteristics of these data (origin, sampling rate, duration and quality of the time series, etc.) add an initial uncertainty that should be considered for the estimation of extreme events. However, in order to focus the discussion on the proposed method, only the sources of uncertainty that arise from the process of directional discretization will be taken into account henceforth.
Independent events were identified by applying the POT method with a time window of 5 days between storms to the omnidirectional data. In this way, a total of 270 storms were isolated. Each storm was characterized by its maximum wind speed ${Y}_{i}^{\mathrm{P}}$, the corresponding direction ${\mathit{\theta}}_{i}^{\mathrm{P}}$, and its angular distance traveled $\left\mathrm{\Delta}\mathit{\theta}\right$. The magnitude and frequency of occurrence of the variable (Fig. 3a) suggest that direction is a relevant covariable for the characterization of extreme events. Figure 3b shows the maximum angular distance traveled by each storm depending on ${\mathit{\theta}}_{i}^{\mathrm{P}}$. For this calculation, the time evolution curve of the direction of each storm event was reconstructed and the absolute maximum difference of the wind direction that can be found between any two points in time within a given storm, taking into account the direction of rotation (clockwise or counterclockwise), was evaluated.
There were significant variations in direction with regard to the values where the peaks occurred. More specifically, there were displacements greater than 45^{∘} in 12 % of the storm events, and onethird of them (black dots) have maximum associated wind speeds higher than those in the 90th percentile. This indicated that storm events can extend over more than one directional sector and there is, therefore, a potential dependence between the extreme values of neighboring sectors.
To take into account this directional dissipation in the extremevalue modeling (Jonathan and Ewans, 2007), for every storm, the peak of the wind speed for each one of the sectors that the storm passes through was obtained. The definition of POT events was based on the same threshold obtained from omnidirectional data, which was selected with the method in Solari et al. (2017).
3.3 Analytical framework
The generalized extreme value (GEV) model is often chosen to describe the extremes of natural agents in wind engineering (Brabson and Palutikof, 2000; Gatey and Miller, 2007; Sacré et al., 2007; Torrielli et al., 2013; Valamanesh et al., 2015) and also in several other branches of civil engineering and geosciences. In line with this, a Poisson–Pareto model (Eq. 6) was used to characterize annual maximum values in this work.
where ξ, $\stackrel{\mathrm{\u0303}}{\mathit{\sigma}}$, and u are, respectively, the parameters of form, scale, and location (threshold) of the generalized Pareto distribution (GPD), which is fit based on a POT regime (Hosking and Wallis, 1987), and where ν is the Poisson parameter, which describes the annual mean rate of occurrence of these events.
To consider the displacement of the storms among sectors, the distribution of the annual maxima in a given sector s was calculated according to the next steps.

Storms were identified as the clusters of sequential values of the omnidirectional wind speed exceeding a given threshold, with a time lag of at least 5 days between their peaks to ensure their independence. In this way, the sequences of wind speeds and directions of the 270 omnidirectional storms were isolated.

From the set of 270 storms, the subset of those whose direction belongs at some point to the sector under consideration was selected. The number of these storms was n_{s}≤270.

For each one of the n_{s} storms, the maximum wind speed whose direction belongs to the sector s was selected. This set of maximum values was the sample m_{s}.

A GPD with parameters (ξ, $\stackrel{\mathrm{\u0303}}{\mathit{\sigma}}$, u) was fitted to the sample m_{s} and the Poisson parameter ν was calculated.

The Poisson–Pareto model from Eq. (6) was used for describing the distribution of the annual maxima in each sector. From this distribution, any return level can be inferred.
3.4 Values adopted for the definition of requirements and indicators
The power curves of the Anderson–Darling test (Anderson and Darling, 1952) and the KS test (Kolmogoroff, 1941; Smirnoff, 1939) are used to define the minimum number of data in each sector and subsector, respectively. Figure 4 shows these curves, which were obtained for this research by simulation (see Appendix A for more details) for a significance level of α=0.05. The effect size was stated as the absolute displacement between the mean value of the population defining the null hypothesis and the mean value of the population from which the contrasted sample was extracted in each simulation (Kottegoda and Rosso, 2008). Circles, squares, and triangles correspond, respectively, to low (0.25σ), medium (0.50σ), and high (0.75σ) effect sizes, for which σ is the standard deviation of the reference population for the null hypothesis. As seen in Fig. 4a, for the usual value of β=0.2 (probability of false negative) and a medium effect size, the number of data in a sector has to be higher than 30. This value is too low for the KS test among subsamples of a sector to be reliable (Fig. 4b). According to this, a minimum number of 60 data was chosen for sectors and (see Fig. 4c for a high effect size) 25 for subsectors.
Furthermore, the study did not consider any division containing sectors that rejected the null hypothesis of the Anderson–Darling test (Anderson and Darling, 1952), with a significance level of α=0.05. To evaluate the $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{2}}}$ indicator, a reference return period of T_{r}=100 years and admissible maximum discrepancy of $\pm {\mathit{\epsilon}}_{\mathrm{0}}=\mathrm{10}$ % in regard to the estimated value were used.
Finally, some practical limitations to the size of the sectors were considered for this case study in order to reduce the range of divisions considered and to limit computational costs. Specifically, the sector amplitude was restricted to the range from 30 to 300^{∘} and only those sectors whose amplitude was a multiple of 5^{∘} were considered.
3.5 Effect of the requirements and variation in indicators, depending on directional sectors
The effect of different criteria for sector selection on the extremevalue models used to fit the available data was characterized. From now on, the following nomenclature is used to present the results: C0 is the criterion proposed in this work (whose definition is summarized in Sect. 2.3) and T90 and T45 are the comparison criteria, which consist of sectors with a constant width of 90 and 45^{∘}, respectively, and a northern direction of origin. Additionally, the definition of criteria C1–C3 also follows the procedure that is summarized in Sect. 2.3, but at point 4b of the aforementioned procedure, indicators $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{1}}}$, $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{2}}}$, and $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{3}}}$ are, respectively, used instead of the overall indicator $\u2225\stackrel{\mathrm{\u203e}}{{p}_{i}}\u2225$.
When applying criteria C0–C3, the selection requirements (Sect. 2.1.1) reduce the number of candidate divisions to 15 973. From these divisions, 58.5 % correspond to threesector divisions, 41.4 % to foursector divisions, and 0.1 % to fivesector divisions. The divisions resulting from each criterion are listed in Table 1. It should be highlighted that only sector S_{3} of criterion T90 and sectors S_{5} and S_{6} of criterion T45 meet the preselection requirements imposed on the other ones (C0 to C3). This leads to a bias in the guarantees for modeling the directional extreme values given by both sets of criteria and should be kept in mind when judging their results.
Figures 5 and 6 show the characteristics of the extreme values in each division. Wind direction is represented on the x axis, where north is zero, and wind magnitude is represented on the y axis. Each graph presents the sectors that correspond to one of the criteria, as well as the box plots, which show the median, the upper and lower quartiles, and the variability in the estimated 100year return values in each sector. The sample of estimations was obtained by means of bootstrapping techniques. For this purpose, the omnidirectional storms were resampled with replacement. The sequence of speeds and directions of each storm remained fixed during each resampling and the size of the resample was always 270 (the original number of storms). Next, the directional 100year return values from the resample were computed, and this routine was repeated 10 000 times to obtain a precise estimate of the bootstrap distribution of the statistic.
Also, for each criterion there is a scatter plot showing the data that were used for the fit of the directional extreme values. During any given storm, wind direction may vary in more than one sector and, in these cases, every storm produces more than one extreme value (one for each sector in which it has data). The number of points in each sector is indicated with the letter N. These points are shown in blue and red. Blue points are the peak values of the omnidirectional storms. Hence, there are 270 blue points summed over all sectors. The red ones are the maxima in each sector of those storms whose omnidirectional peak occurred in a different sector. These points introduce dependency among the extremes of each sector, and the number of them is indicated with the letter n. Finally, threshold exceedances that do not take part in the fit are depicted in gray.
A comparison of the accuracy of the extremevalue models that were used to fit the directional data of each criterion is shown in Fig. 7. It depicts the quantile plots for the criteria T90 (row 1), T450 (rows 2 and 3), and C0 (row 4), for which the x axis corresponds to the empirical data and the y axis to the models.
Figure 8 measures the performance of each solution obtained in regard to indicators $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{1}}}$, $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{2}}}$, and $\stackrel{\mathrm{\u203e}}{{p}_{\mathrm{3}}}$. Each indicator is represented along its respective axis, which has its origin in the center. All axes are arranged radially (with equal distances from each other) and all of them have the same scale of 0–1. To enhance the understanding of the graphs, the data are connected to form a polygon, and circles of isovalue are also represented. Table 2 shows the values for each indicator for the different criteria.
Criteria C0 to C3 lead to divisions with three sectors in all cases: a larger one, which roughly covers the W–SE region, and two more in the range where larger and more frequent storms occur. These divisions are consistent with the analysis of regional wind characteristics. Furthermore, the divisions of criteria T90 and T45 show worse results in all indicators with striking differences in intrasectorial homogeneity and independence of the sectorial extremes.
This section evaluates the effect of directional sector selection on design values and structure reliability. For this purpose, we used the simple example of a structure with three straight sections whose design wind speeds should be adapted to the directional variability in the extreme values of the agent. The normal directions of the sections form angles of 60, 180, and 300^{∘} in relation to the north. For ease of exposure, the following working hypotheses are assumed.

Failure of the whole structure occurs when at least one of the sections fails.

The failure mode does not depend on the direction of the agent's incidence but rather on the section type. In this case, the failure in each section occurs when wind action in the normal direction ±22.5^{∘} exceeds a given design value and is independent of the failure of the other sections.

The response coefficients of the structure are all equal to 1.

Each directional sector isolates a population of the agent's extreme values with homogeneous characteristics.
Given the requirement that the overall failure probability in the useful life of the structure is lower than a given value P_{f,V}, there is an infinite number of compatible criteria that can define the failure probability of each section (Forristall, 2005). Jonathan and Ewans (2007) propose fixing these probabilities by minimizing the total cost C of the structure, which they define as an arbitrary function of the value of the design agent expressed as $C=K\sum _{n=\mathrm{1}}^{N}{x}_{n}^{\mathrm{2}}$, where x_{n} is the design value in each section and K is a constant. This research proposes an alternative function C that incorporates two summands: (i) the construction cost C_{c}(x_{n}), which depends on the value of the design agent, and (ii) the risk at each section obtained as the product of its probability of failure ${P}_{{\mathrm{f}}_{n},\mathrm{V}}$ and its consequences c_{n} (Losada, 2010) (Eq. 7).
We compared the design obtained with the sectors defined according to criterion C0 with the result of applying (a) the omnidirectional analysis (in which the design value of the wind speed is the same for the three sections) and (b) the sectorial divisions obtained from criteria T90 and T45. For each section and criterion, Fig. 9 shows the range of directions that can cause failure (in gray) as well as the directional sectors involved.
Assuming a section n, which is affected by a number S of directional sectors, the probability of an annual failure ${P}_{{\mathrm{f}}_{n},\mathrm{1}}$ is obtained with Eq. (8). This equation expresses the complementary value that the annual maximum of the agent not exceed the design value x_{n} in any of the subsectors s (which are assumed to be independent) and where ν_{s} is the Poisson parameter, and ξ_{s} and $\stackrel{\mathrm{\u0303}}{{\mathit{\sigma}}_{\mathrm{s}}}$ are, respectively, the form and scale parameters of the fitted generalized Pareto distribution in this subsector.
For a maximum admissible failure probability of p_{0} and a useful life of V years (Eq. 9), the following optimization problem was formulated:
subject to
where N is the number of sections, ${P}_{{\mathrm{f}}_{n},\mathrm{1}}$ is provided by Eq. (8), and x_{s} is the design value in each of the subsectors that affect the section. For the objective function C, we adopted the expression given by Eq. (10). In this expression, K=0.025 such that the design cost for a wind speed of 20 m s^{−1} is 10. The value of the consequences is related to the admissible maximum failure probability in the useful life of the structure (Losada, 2002). Accordingly, c_{n}=50 was adopted for p_{0}≤0.2 (very low repercussions) and c_{n}=100 for p_{0}≤0.1 (low repercussions); thus the risk is 10 in both cases.
4.1 Extremevalue models
For the omnidirectional analysis we fit a GPD to the omnidirectional POT regimen. Next, we used a Poisson–Pareto model to estimate the distribution for the annual maxima in the range of directions that can cause failure of each sector. To take into account the width of the resulting directional ranges, the Poisson parameter was evaluated into them. For the directional results we followed the same scheme but the GPD was fit to the directional POT regimes according to the divisions of each criterion.
Table 3 shows the characteristics of the extremevalue models that intervene in the optimization problem of each criterion. The differences among criteria can be seen, for example, in the upper bound (u^{+}) for wind speed in each section, which is limited by $u\stackrel{\mathrm{\u0303}}{{\mathit{\sigma}}_{\mathrm{s}}}/{\mathit{\xi}}_{\mathrm{s}}$ if ξ_{s}≤0. The greater discrepancies can be found in section 1, where this bound is 48.6 m s^{−1} for criterion T90, 23.3 m s^{−1} for C0, and it does not exist for T45. For measuring how well the GPD fits the input data, the last two columns show, respectively, the statistic K and the critical value of the KS goodnessoffit test with a significance level of 0.05. In all cases, the test statistic is less than the critical value.
4.2 Optimization and design wind speeds
The optimization problem was solved with an interior point algorithm (Byrd et al., 2000). Table 4 shows the design wind speeds obtained in each section, depending on the criterion (C0, T90, T45, and omnidirectional). The upper rows of the table show the results for an admissible maximum failure probability in V=50 years of p_{0}≤0.2, whereas the lower rows show the results for p_{0}≤0.1.
All the comparison criteria (T90, T45, and omnidirectional) show design wind speeds for each section that differs from those of criterion C0. Consequently, directional sector selection can be decisive in the project design if cost is a relevant factor. The greatest discrepancies occurred in section 1. With criterion T90, there are variations of 6.54 % with p_{0}≤0.2 and of 8.67 % with p_{0}≤0.1. With criterion T45, there are variations of 19.36 % for p_{0}≤0.2 and of 25.24 % for p_{0}≤0.1. With the omnidirectional criterion, variations are 5.91 % and 5.70 %, respectively.
By definition, the design wind speeds corresponding to each criterion fulfill the requirements of the optimization problem, in accordance with their respective probability models. However, only the sectors of criterion C0 have been selected objectively in consonance with the working hypothesis of the directional model for the extremes and, therefore, they offer better guarantees for dimensioning. Thus, in order to compare the impact of design wind speeds on both the failure probability during the useful life of the structure and the cost function (Eq. 10), the extremevalue model corresponding to C0 was used as a reference.
Table 5 indicates the total failure probability in the useful life of the structure and the result of the cost function. These values were calculated by entering the design wind speeds of each criterion in the directional model obtained from C0. The first rows show the results for p_{0}≤0.2, and the last ones show those for p_{0}≤0.1.
Solving the optimization problem for criterion C0 led to solutions far from the edge of the validity region. The design wind speeds obtained with the other criteria increase the probability of failure but fulfill the design requirements, with the exception of the T90 criterion. Particularly noteworthy is the result with T90 for p_{0}≤0.1, which almost doubles the maximum acceptable probability of failure during useful life. Regarding the cost function, notable differences can be found, with increases by 26.7 %, 12.6 %, and 3.7 % for T90, T45, and the omnidirectional criterion, respectively, for p_{0}≤0.2 and 55.8 %, 18.9 %, and 4.6 % for p_{0}≤0.1. These differences show that the selection of directional sectors can have significant implications for the calculation of structure reliability and costs and thus should be included as an integral part of project design.
On a final note, the selection of the threshold is an additional source of uncertainty that can affect the results. Different thresholds imply different definitions of what is an extreme value and hence result in different directional sectors. If there is no strong criterion for an a priori selection of the threshold, a sensitivity analysis of the results is recommended. In this situation, p_{0} could serve as an indicator for the final choice of the threshold. Additionally, preliminary analysis suggests that the calculation of reliability may also be sensitive to the directional variability in the threshold. Nevertheless, a deeper study is still needed to properly incorporate the effect of this variability on the definition of homogeneous and independent sectors and its impact on the uncertainty of the results.
This paper has described a procedure for the selection of directional sectors in a nonarbitrary manner, considering the following sources of uncertainty: (1) the validity of the model used to characterize the extreme behavior of the sector samples, (2) the goodness of parameter estimation, (3) the capacity of each model to represent extreme behavior in the total amplitude of the corresponding sector, and (4) the validity of the working hypothesis of the independence among extreme values in different sectors.
This research led to the following conclusions. Firstly, the results of modeling the directional extreme behavior of natural agents can be affected by the choice of directional sectors used for calculation. Secondly, the selection of sectors without considering the extreme properties of the data negatively affects the confidence in the estimates on which the project design is based. This makes the use of sectors of equal amplitude not recommended, without sufficient justification. In this sense, the method presented in this research is an objective tool for the selection of directional sectors, which also facilitates the application of standard calculation procedures since it leads to homogeneous and uncorrelated sectors. The results obtained show that it offers better guarantees for dimensioning than the use of more conventional engineering approaches based on divisions arbitrarily chosen because it reduces the sources of uncertainty in the estimation of design values. Furthermore, this method also assures that sector division by direction is in consonance with the working hypotheses of the directional model. This means that quantification of probabilities is applied within the validity range of this model.
The method was applied to the selection of directional sectors for the calculation of the design wind speed of a structure located at the mouth of the Río de la Plata. The impact that choice of method would have on the failure probability during the useful life of a structure was analyzed, and the results with the proposed method were compared to those based on divisions with equal size sectors and a northern direction of origin. It was found that the procedure followed can have significant repercussions on the cost estimate and reliability, and thus condition the viability of an investment project. Consequently, decisions regarding sector selection should be an integral part of the project design process.
The data used in this study are available in Dee et al. (2011).
The procedure for obtaining the power curves for the Anderson–Darling test, whose null hypothesis, H_{0}, is that the sample belongs to a population with a distribution function, F(x)∼GPD(ξ, $\stackrel{\mathrm{\u0303}}{\mathit{\sigma}}$, u) with mean μ and standard deviation σ, was the following:

select the significance level α and effect size c;

define the parameters of a generalized Pareto distribution $G\left(x\right)\sim \mathrm{GPD}({\mathit{\xi}}^{*}$, ${\stackrel{\mathrm{\u0303}}{\mathit{\sigma}}}^{*}$, u) with mean value ${\mathit{\mu}}^{*}=\mathit{\mu}+c$ and standard deviation σ;

simulate a number N of random samples with a distribution function G(x) for each sample size of interest;

obtain the result (rejection or nonrejection) of the Anderson–Darling test for each simulated sample;

obtain the value of β for each size as the quotient of the number of positive results and the total number of simulations.
Similarly, the power curves for a KS test whose null hypothesis, H_{0}, is that two samples belong the same population, can be obtained as follows:

select the significance level α of the effect size c and of a sample size M;

define the parameters for two generalized Pareto distributions: (i) $F\left(x\right)\sim \mathrm{GPD}(\mathit{\xi},\stackrel{\mathrm{\u0303}}{\mathit{\sigma}},u)$ with mean μ and standard deviation σ, (ii) $G\left(x\right)\sim \mathrm{GPD}({\mathit{\xi}}^{*}$, ${\stackrel{\mathrm{\u0303}}{\mathit{\sigma}}}^{*}$, u) with mean ${\mathit{\mu}}^{*}=\mathit{\mu}+c$ and standard deviation;

simulate a number N of random samples with distribution functions F(x) and G(x) for each value of $\stackrel{\mathrm{\u0303}}{m}=\mathrm{min}m$, ${m}^{\prime}$ of interest, where m and m^{′} are, respectively, the sample sizes of F(x) and G(x), and $m+{m}^{\prime}=M$;

obtain the result (rejection or nonrejection) of the KS test for each pair of simulated samples;

obtain the value of β for each size $\stackrel{\mathrm{\u0303}}{m}$ as the quotient of the number of positive results and the total number of simulations.
MAL and PF had the initial idea for the study. PF developed the method, performed the data analysis and wrote the initial paper. SS provided theoretical support and implemented several statistical tools. All authors discussed the results and provided ideas, comments and suggestions to improve the article. MAL supervised and directed the research.
The authors declare that they have no conflict of interest.
The doctoral studies that led to this work were partially funded by Abengoa
Research within the framework of a cooperation agreement between the company
and the Environmental Fluid Dynamics Research Group of the University of Granada.
Edited by: Mauricio Gonzalez
Reviewed by: two anonymous referees
Anderson, T. W. and Darling, D. A.: Asymptotic theory of certain `goodnessoffit' criteria based on stochastic processes, Ann. Math. Stat., 23, 193–212, https://doi.org/10.1214/aoms/1177729437, 1952. a, b, c
API: API RP 2AWSD: Recommended Practice for Planning, Designing and Constructing Fixed Offshore PlatformsWorking Stress Design, vol. 21, American Petroleum Institute, Washington, 2000. a, b
Brabson, B. and Palutikof, J.: Tests of the generalized Pareto distribution for predicting extreme wind speeds, J. Appl. Meteorol., 39, 1627–1640, 2000. a
Byrd, R. H., Gilbert, J. C., and Nocedal, J.: A trust region method based on interior point techniques for nonlinear programming, Math. Program., 89, 149–185, 2000. a
Coles, S. G.: An introduction to Statistical Modeling of Extreme Values, Springer, London, https://doi.org/10.1007/9781447136750, 2001. a, b
Coles, S. G. and Walshaw, D.: Directional Modelling of Extreme Wind Speeds, J. Roy. Stat. Soc. Ser. C, 43, 139–157, https://doi.org/10.2307/2986118, 1994. a
Cook, N. J.: Towards better estimation of extreme winds, J. Wind Eng. Indust. Aerodynam., 9, 295–323, https://doi.org/10.1016/01676105(82)900216, 1982. a
Cook, N. J.: Note on directional and seasonal assessment of extreme winds for design, J. Wind Eng. Indust. Aerodynam., 12, 365–372, https://doi.org/10.1016/01676105(83)900570, 1983. a
Cook, N. J. and Mayne, J. R.: A novel working approach to the assessment of wind loads for equivalent static design, J. Wind Eng. Indust. Aerodynam., 4, 149–164, https://doi.org/10.1016/01676105(79)900436, 1979. a
Cook, N. J. and Mayne, J. R.: A refined working approach to the assessment of wind loads for equivalent static design, J. Wind Eng. Indust. Aerodynam., 6, 125–137, https://doi.org/10.1016/01676105(80)900264, 1980. a
Cook, N. J. and Miller, C. A.: Further note on directional assessment of extreme winds for design, J. Wind Eng. Indust. Aerodynam., 79, 201–208, https://doi.org/10.1016/S01676105(98)001093, 1999. a
Dee, D. P., Uppala, S. M., Simmons, A. J., Berrisford, P., Poli, P., Kobayashi, S., Andrae, U., Balmaseda, M. A., Balsamo, G., Bauer, P., Bechtold, P., Beljaars, A. C. M., van de Berg, L., Bidlot, J., Bormann, N., Delsol, C., Dragani, R., Fuentes, M., Geer, A. J., Haimberger, L., Healy, S. B., Hersbach, H., Hólm, E. V., Isaksen, L., Kållberg, P., Köhler, M., Matricardi, M., Mcnally, A. P., MongeSanz, B. M., Morcrette, J. J., Park, B. K., Peubey, C., de Rosnay, P., Tavolato, C., Thépaut, J. N., and Vitart, F.: The ERAInterim reanalysis: Configuration and performance of the data assimilation system, Q. J. Roy. Meteorol. Soc., 137, 553–597, https://doi.org/10.1002/qj.828, 2011. a, b
DNV: DNVRPC205: Environmental Conditions and Environmental Loads, Det Norske Veritas, Norway, 2010. a, b
Forristall, G. Z.: On the Use of Directional Wave Criteria, J. Waterway Port Coast. Ocean Eng., 130, 272–275, https://doi.org/10.1061/(ASCE)0733950X(2004)130:5(272), 2005. a
Framiñan, M. B., Etala, M. P., Acha, E. M., Guerrero, R. A., Lasta, C. A., and Brown, O. B.: Physical characteristics and processes of the Río de la Plata estuary, Estuar. South Am., 2, 161–194, 1999. a
Gatey, D. and Miller, C.: An investigation into 50year return period wind speed differences for Europe, J. Wind Eng. Indust. Aerodynam., 95, 1040–1052, 2007. a
Guerrero, R. A., Acha, E. M., Framiñan, M. B., and Lasta, C. A.: Physical oceanography of the Río de la Plata Estuary, Argentina, Cont. Shelf Res., 17, 727–742, https://doi.org/10.1016/S02784343(96)000611, 1997. a
Holmes, J. D.: Wind loading of structures, CRC Press, Boca Raton, FL, 2015. a
Hosking, J. and Wallis, J.: Parameter and Quantile Estimation for the Generalized Pareto Distribution, Technometrics, 29, 339–349, https://doi.org/10.1198/016214507000000932, 1987. a
Irwin, P., Garber, J., and Ho, E.: Integration of wind tunnel data with full scale wind climate, in: Proceedings of the 10th Americas Conference on Wind Engineering, May 2005, Baton Rouge, Louisiana, USA, 132–135, 2005. a
ISO: ISO 199011:2005: Petroleum and natural gas industries – Specific requirements for offshore structures – Part 1: Metocean design and operating considerations, International Organization for Standards, 2005. a, b
Isyumov, N., Ho, E., and Case, P.: Influence of wind directionality on wind loads and responses, J. Wind Eng. Indust. Aerodynam., 133, 169–180, 2014. a
Jonathan, P. and Ewans, K.: The effect of directionality on extreme wave design criteria, Ocean Eng., 34, 1977–1994, https://doi.org/10.1016/j.oceaneng.2007.03.003, 2007. a, b
Kolmogoroff, A.: Confidence limits for an unknown distribution function, Ann. Math. Stat., 12, 461–463, https://doi.org/10.1214/aoms/1177731684, 1941. a, b, c, d
Kottegoda, N. T. and Rosso, R.: Applied Statistics for Civil and Environmental Engineers, Blackwell Malden, MA, 2008. a
Losada, M. Á.: ROM 0.0: General Procedure and Requirements in the Design of Harbor and Maritime Structures, Puertos del Estado, Spain, 2002. a
Losada, M. Á.: ROM 1.0: Breakwaters Recommendations (Part I: Calculation and Project Factors. Climatic Agents), Puertos del Estado, Spain, 2010. a
Mayne, J.: The estimation of extreme winds, J. Wind Eng. Indust. Aerodynam., 5, 109–137, 1979. a
Sacré, C., Moisselin, J., Sabre, M., Flori, J., and Dubuisson, B.: A new statistical approach to extreme wind speeds in France, J. Wind Eng. Indust. Aerodynam., 95, 1415–1423, 2007. a
Simionato, C., Meccia, V., Guerrero, R., Dragani, W., and Nuñez, M.: Rio de la Plata estuary response to wind variability in synoptic to intraseasonal scales: 2. Currents' vertical structure and its implications for the salt wedge structure, J. Geophys. Res.Oceans, 112, C07005, https://doi.org/10.1029/2006JC003815, 2007. a
Simiu, E., Hendrickson, E. M., Nolan, W. A., Olkin, I., and Spiegelman, C. H.: Multivariate Distributions of Directional Wind Speeds, J. Struct. Eng., 111, 939–943, https://doi.org/10.1061/(ASCE)07339445(1985)111:4(939), 1985. a
Smirnoff, H.: Sur les Écarts de la Courbe de la Distribution Empirique, Receuil Mathémathique, 6, 3–26, 1939. a, b, c, d
Solari, S. and Alonso, R.: A new methodology for extreme waves analysis based on weatherpatterns classification methods, Coas. Eng. Proc., 1, 23, https://doi.org/10.9753/icce.v35.waves.23, 2017. a
Solari, S. and Losada, M. Á.: Simulation of nonstationary wind speed and direction time series, J. Wind Eng. Indust. Aerodynam., 149, 48–58, https://doi.org/10.1016/j.jweia.2015.11.011, 2016. a, b
Solari, S., Egüen, M., Polo, M. J., and Losada, M. A.: Peaks Over Threshold (POT): A methodology for automatic threshold estimation using goodness of fit pvalue, Water Resour. Res., 53, 2833–2849, 2017. a
Torrielli, A., Repetto, M. P., and Solari, G.: Extreme wind speeds from longterm synthetic records, J. Wind Eng. Indust. Aerodynam., 115, 22–38, 2013. a
Valamanesh, V., Myers, A., and Arwade, S.: Multivariate analysis of extreme metocean conditions for offshore wind turbines, Struct. Safety, 55, 60–69, 2015. a
Wasserstein, R. L. and Lazar, N. A.: The ASA's statement on pvalues: context, process, and purpose, Am. Stat., 70, 129–133, https://doi.org/10.1080/00031305.2016.1154108, 2016. a
Zhang, X. and Chen, X.: Assessing probabilistic wind load effects via a multivariate extreme wind speed model: A unified framework to consider directionality and uncertainty, J. Wind Eng. Indust. Aerodynam., 147, 30–42, 2015. a
Zhang, X. and Chen, X.: Influence of dependence of directional extreme wind speeds on wind load effects with various mean recurrence intervals, J. Wind Eng. Indust. Aerodynam., 148, 45–56, 2016. a